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Estimation of sex from the
morphometric assessment of hand
bones in a Western Australian
population
Rebecca DeSilva (BSc, GDipForSci)
Centre for Forensic Science
University of Western Australia
This thesis is presented for the degree of
Master of Forensic Science
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DECLARATION
I declare that the research presented in this thesis, for the Master of Forensic
Science at the University of Western Australia, is my own work. The results of the
work have not been submitted for assessment, in full or part, within any other
tertiary institute, except where due acknowledgement has been made in the text.
………………………………………………
Rebecca DeSilva
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ABSTRACT
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ABSTRACT
The role of a forensic anthropologist in medico-‐legal investigations is to, ultimately
contribute toward establishing the identity of unknown skeletal remains by
constructing a biological profile; which involves estimations of sex, age, stature
and ancestry. Recent research relating to the formulation of sex estimation
standards has focussed on the morphological assessment of bones other than the
pelvis and cranium, such as the long bones of the appendicular skeleton. In
particular, sex estimation standards based on morphometric data from the
metacarpals and phalanges have reported classification accuracy rates of 80% and
above. As it has been established that the application of foreign skeletal standards
can result in the misclassification of sex, the purpose of this study is to produce
population specific sex estimation standards for a contemporary Western
Australian population. The age at which hand bones are metrically sexually
dimorphic is also examined to determine the minimum age at which sex can be
reliably estimated.
The present study examines digital right hand x-‐rays of 300 adults and 100 sub-‐
adults, equally represented by sex. A total of 40 measurements are taken in the
metacarpals and proximal phalanges of each hand x-‐ray using the OsiriX®
software. The measurements are analysed using univariate statistics and cross-‐
validated direct and stepwise discriminant function analysis. In the adult sample,
all of the hand bone measurements were significantly dimorphic with a tendency
for the width measurements to express a higher degree of sexual dimorphism than
the length measurements. A maximum classification accuracy of 91.00% was
achieved (using a stepwise discriminant function consisting of 8 measurements)
with a sex bias of -‐6.00%. Analysis of the sub-‐adult data suggested that the hand
bones start to become metrically sexually dimorphic between the ages of 14 to 15
years; stepwise discriminant function analysis produced a maximum classification
accuracy of 95.00%, with a sex bias of 10.00%. However, when attempting to
classify sex in sub-‐adults using an adult function, males were likely to be
misclassified as females, and the highest classification achieved was 65.00% with a
sex bias of -‐35.00%. This would suggest that the functions developed using adult
ABSTRACT
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data are not forensically viable for sex estimation in sub-‐adult skeletal remains in a
Western Australian population.
The results of the current study indicate that sex can be accurately estimated
based on the morphometric analysis of hand bones in a Western Australian
population. The cross-‐validated classification accuracies are both within the
acceptable range of classification accuracies previously published for sex
estimation based on morphometric hand bone data and comparable to
classification accuracy ranges found for other skeletal elements such as the skull. It
also demonstrates that the hand bones start to express sexual dimorphism in sub-‐
adults from the age of 14 years. The standards produced from this study can be
used in forensic investigations that require sex estimation standards specific to a
Western Australian population.
ACKNOWLEDGEMENTS
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ACKNOWLEDGEMENTS
This project, which has been overwhelming at times, has been made possible by
the never-‐ending support of my family, peers and supervisors. I will now take a
moment to express my gratitude and utmost appreciation to anyone that has
helped me along the way over this past year.
Professional Acknowledgements
First, I would like to thank my co-‐ordinating supervisor, Professor Daniel Franklin
and my co-‐supervisor, Miss Ambika Flavel for their patience, understanding and
the wealth of knowledge they did not hesitate to share throughout the duration of
my post-‐graduate studies. As a team, they were able to provide constructive
criticism that was both balanced and productive. I would have not been able to
reach my full potential without their efforts
I would also like to thank those that have provided academic and administrative
support during my time at the Centre for Forensic Science; in particular Professor
Ian Dadour, the director of the Centre for Forensic Science, Mr Algis Kuliukas and
Miss Bonnie Knott. I am grateful for the resources made accessible by the Centre of
Forensic Science to complete this research and also for the technical support
readily available when any issues arose. Thank you to Adjunct Associate Professor
Robin Hart as well, for providing digital hand x-‐rays from the Picture Archiving
and Communication Systems (PACS) database with efficiency and resolving any
issues that occurred without hesitation.
Lastly, I would like to thank my peers; specifically Alex, Elsie, Siobhan and other
members of the ‘forensic anthropology research group’ at the Centre for Forensic
Science. My peers not only provided different perspectives and academic
assistance, they made this year of post-‐graduate study seem less impossible.
ACKNOWLEDGEMENTS
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Personal Acknowledgements
First and foremost I would like to thank my family; my mum and sister, Michelle
and Taylor, for being incredibly supportive for the entire duration of my tertiary
studies and for their undying love, encouragement and patience. Special thanks
also goes to Dave for his contagious optimism and for always showing a genuine
interest in this research project. I also wish to acknowledge my partner David for
listening to my intolerable ramblings and always providing a shoulder to lean on.
To all of the above people, thank you!
Finally, to family, friends and anyone that was the victim of one of my many thesis
tangents, thank you for listening.
TABLE OF CONTENTS
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TABLE OF CONTENTS
DECLARATION ......................................................................................................................... i
ABSTRACT .............................................................................................................................. iii
ACKNOWLEDGEMENTS ........................................................................................................ v
Professional Acknowledgements ............................................................................................. v
Personal Acknowledgements .................................................................................................... vi
TABLE OF CONTENTS ........................................................................................................ vii
LIST OF FIGURES ................................................................................................................... xi
LIST OF TABLES ................................................................................................................. xiii
CHAPTER ONE ......................................................................................................................... 1
Introduction: research objectives and outline ............................................................ 1 1.1 The modern role of forensic anthropology .................................................................... 1
1.2 The estimation of skeletal sex ............................................................................................ 2
1.2.1 Sex estimation potential of the metacarpals ......................................................................... 3
1.3 Research aims .......................................................................................................................... 4
1.4 Data collection ......................................................................................................................... 5
1.5 Limitations ................................................................................................................................ 6
1.6 Thesis outline ........................................................................................................................... 7
CHAPTER TWO ....................................................................................................................... 9
A brief introduction to the anatomy of the hand ........................................................ 9
2.1 Introduction .............................................................................................................................. 9
2.2 Skeletal anatomy of the hand .............................................................................................. 9
2.3 Anatomical position and directionality ......................................................................... 10
2.4 Muscles acting on the hand ................................................................................................ 12
2.4.1 Anterior compartment of the forearm ................................................................................. 12
2.4.2 Posterior compartment of the forearm ................................................................................ 16
2.4.3 Intrinsic muscles of the hand ................................................................................................... 19
CHAPTER THREE ................................................................................................................ 21
Sexual dimorphism and sex estimation methods: a review of previous
research ................................................................................................................................. 21 3.1 Introduction ............................................................................................................................ 21
TABLE OF CONTENTS
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3.2 Sexual dimorphism .............................................................................................................. 21
3.2.1 The pelvis .......................................................................................................................................... 22
3.2.2 The skull ............................................................................................................................................. 23
3.2.3 Long bones ........................................................................................................................................ 24
3.3 Sex estimation based on the analysis of the hand ..................................................... 24
3.3.1 Fleshed hand .................................................................................................................................... 25
3.3.2 Hand bones ....................................................................................................................................... 28
CHAPTER FOUR ................................................................................................................... 33
Materials and Methods ..................................................................................................... 33
4.1 Introduction ........................................................................................................................... 33
4.2 Materials ................................................................................................................................. 33
4.3 Methods ................................................................................................................................... 34
4.3.1 Landmark definitions and typology ....................................................................................... 34
4.3.2 Measurement definitions ........................................................................................................... 36
4.3.3 Measurement acquisition – OsiriX® ....................................................................................... 37
4.4 Statistical analyses: precision test ................................................................................. 39
4.5 Statistical analyses: measurement data ....................................................................... 42
4.5.1 Normality tests ................................................................................................................................ 42
4.5.2 Significance tests ............................................................................................................................ 43
4.5.3 Discriminant function analyses ............................................................................................... 44
CHAPTER FIVE ..................................................................................................................... 49
Results .................................................................................................................................... 49
5.1 Introduction ........................................................................................................................... 49
5.2 Measurement precision ..................................................................................................... 49
5.3 Descriptive statistics for the adult data ........................................................................ 52
5.3.1 Age distribution .............................................................................................................................. 52
5.3.2 Measurement Normality ............................................................................................................. 52
5.3.3 Univariate comparisons .............................................................................................................. 53
5.3.4 Discriminant function analyses ............................................................................................... 56
5.3.5 Posterior probabilities ................................................................................................................. 58
5.4 Population differences ....................................................................................................... 62
5.4.1 Measurement differences ........................................................................................................... 62
5.4.2 Variation in the expression of sexual dimorphism ......................................................... 63
5.4.3 Classification accuracy ................................................................................................................. 64
5.5 Sub-‐adult analyses ............................................................................................................... 65
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5.5.1 Age distribution .............................................................................................................................. 65
5.5.2 Measurement normality ............................................................................................................. 65
5.5.3 Univariate comparisons .............................................................................................................. 66
5.6 Sex classification accuracy in the sub-‐adult hand ...................................................... 66
5.7 Interaction effects ................................................................................................................. 68
CHAPTER SIX ........................................................................................................................ 69
Discussion and conclusions ............................................................................................ 69
6.1 Introduction ............................................................................................................................ 69
6.2 Measurement precision ...................................................................................................... 69
6.3 Adult data ............................................................................................................................... 71
6.3.1 Sexual dimorphism in the hand ............................................................................................... 71
6.3.2 Morphometric population variation ...................................................................................... 76
6.3.3 Importance of population specific standards .................................................................... 83
6.4 Sub-‐adult sample .................................................................................................................. 84
6.5 Forensic applications .......................................................................................................... 86
6.6 Limitations and future research ...................................................................................... 87
6.7 Conclusions ............................................................................................................................. 88
REFERENCES ........................................................................................................................ 91
Appendix One .................................................................................................................... 105
Appendix Two ................................................................................................................... 109
Appendix Three ................................................................................................................ 111
Appendix Four ................................................................................................................... 113
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LIST OF FIGURES
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LIST OF FIGURES
Figure 2.1 10
Dorsal view of the bones of the right hand.
Figure 2.2 11
Dorsal view of the left hand with terms used to define the anatomical
position of the hand.
Figure 2.3 13
The most superficial layer of muscles in the anterior forearm.
Figure 2.4 15
The second layer of muscle in the anterior forearm.
Figure 2.5 15
The third layer of muscle in the anterior forearm.
Figure 2.6 17
The lateral superficial layer of muscles in the posterior forearm.
Figure 2.7 18
The medial superficial layer of muscles in the posterior forearm.
Figure 2.8 19
The deep muscle layer of posterior forearm.
Figure 4.1 36
Antero-‐posterior view of metacarpal two, metacarpal one and
proximal phalanx one (from left to right) illustrating the eight
landmarks defined in Table 4.2..
Figure 4.2 38
Antero-‐posterior view of metacarpal two illustrating the
measurements acquired for the study; defined in Table 4.3.
LIST OF FIGURES
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LIST OF TABLES
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LIST OF TABLES
Table 2.1 11
Terms used to describe anatomical positioning.
Table 4.1 34
The number of individuals in each age group in the sub-‐adult sample.
Table 4.2 37
Definitions of the landmarks acquired for metacarpal two.
Table 4.3 38
Definitions of acquired measurements for metacarpal two.
Table 5.1 50
Measurement precision (TEM, rTEM & R) for the landmark
measurement method.
Table 5.2 51
Measurement precision (TEM, rTEM & R) for the line-‐tool
measurement method.
Table 5.3 53
Distribution of age (in years) of the adult Western Australian sample.
Table 5.4 54
Descriptive statistics and means comparison of mean hand bone
measurements (in mm).
Table 5.5 57
Direct single variable discriminant analyses of individual hand
bones, including demarking point values (in mm).
Table 5.6 57
Direct multiple variable discriminant analysis of metacarpals.
LIST OF TABLES
xiv
Table 5.7 59
Stepwise discriminant function analysis of the Western Australian
adult sample.
Table 5.8 63
Five comparative populations (including source of data and sample
size).
Table 5.9 64
Classification accuracies when applying foreign standards to a
Western Australian population.
Table 5.10 65
Distribution of age (in years) for each of the three age groups within
the sub-‐adult data sample.
Table 5.11 67
Stepwise discriminant functions based on the analysis of the sub-‐
adult sample.
Table 5.12 68
Sex classification accuracies of adult Function 13 to the sub-‐adult
sample.
Table 6.1 75
Sex classification accuracy of hand bone measurements in a variety
of global populations.
Table 6.2 78
Quality of life statistics, quality of life index and human development
index for each of the five comparative populations.
Table 6.3 82
Year of birth and year of death ranges of the present study and the
three temporally different comparative studies.
LIST OF TABLES
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Table A1.1 105
Posterior probabilities calculated for the adult discriminant
Functions 1 to 18.
Table A2.1 109
Unpaired t-‐test results for the comparison of metacarpal one, two
and four lengths from the current study to four previously published
studies.
Table A3.1 111
Unpaired t-‐test results for the comparison of males and females for
each of the five comparative populations.
Table A4.1 113
Descriptive statistics of mean sub-‐adult hand bone measurements (in
mm) for Group A.
Table A4.2 117
Descriptive statistics of mean sub-‐adult hand bone measurements (in
mm) for Group B.
Table A4.3 121
Descriptive statistics of mean sub-‐adult hand bone measurements (in
mm) for Group C.
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CHAPTER ONE
Introduction: research objectives and outline
1.1 The modern role of forensic anthropology
The use of forensic anthropology in medico-‐legal investigations has become more
common over time, with an increasing number of referred cases involving remains
that are ‘problematic’ for a forensic pathologist (Braz 2009; Dirkmaat et al. 2008).
These ‘problematic’ cases include those, for example, requiring the assessment of
skeletal, partially fleshed, charred or dismembered remains. Forensic
anthropology is the application of concepts derived from the theory and methods
of physical anthropology to a forensic investigative context that requires the
analysis of skeletal remains (Cattaneo 2007; Dirkmaat et al. 2008). The analysis of
human skeletal remains by a forensic anthropologist involves (amongst other
factors) the construction of a biological profile, which aids in establishing a
possible identity in conjunction with missing persons information and other lines
of forensic evidence (SWGANTH 2011; Scheuer 2002).
A biological profile involves estimating sex, age, stature and ancestry through
metric and non-‐metric analyses of skeletal remains. Prior to constructing a
biological profile the forensic anthropologist must first confirm that the remains
are in fact bone and then establish whether or not the skeletal remains are of
human origin (Bass 2005). Once the remains are confirmed to be human in origin,
a biological profile is formulated, which will essentially narrow the pool of possible
matching identities. For example, by estimating sex, a forensic anthropologist
eliminates all individuals present in the potential pool that are of the opposite sex.
As the primary focus of the present thesis is on methods for skeletal sex
estimation, the latter is considered in more detail below.
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1.2 The estimation of skeletal sex
The estimation of skeletal sex is generally the first component of a biological
profile performed because statistics for estimating other biological attributes (e.g.
age, stature and ancestry) are generally sex-‐specific (Braz 2009; Franklin 2010).
Sexual dimorphism is the biological foundation of sex estimation and is defined as
physical and behavioural differences occurring between males and females
(Glücksman 1981; Frayer & Wolpoff 1985). Sex differences in the shape, size and
appearance of bones arise during development according to individual genetic
markers and in response to sex hormones during puberty. This is due to bone
development being dependent on a combination of genetic markers and hormone
exposure (Frayer & Wolpoff 1985). The age at which these sex-‐specific
morphological changes occur is dependent on a number of genetic and
environmental factors that are population specific (Frayer & Wolpoff 1985).
Skeletal sex is estimated using both a metric and/or non-‐metric assessment.
Metric analyses involve taking a series of skeletal measurements that are
compared to pre-‐existing standards relevant to the population concerned (Braz
2009; Stojanowski 1999). The visual analyses of morphological traits (such as the
shape, size and specific bony protrusions or features) are used to estimate sex by
comparing these morphological traits to those that are known to be male or female
(White & Folkens 2005). For example, with regard to sex estimation, non-‐metric
analyses involve the visual assessment of the gross morphology of the pelvis or
skull, which are both known to be sexually dimorphic. More specifically, with
regards to the pelvis, such an assessment of traits could involve applying the
Phenice (1969) method. This method is based on assessing whether certain
morphological traits (ventral arc; subpubic concavity; medial aspect of the
ischiopubic ramus) are present in the pelvis (Phenice 1969). Metric analyses of
those same bones would involve taking defined measurements and inputting them
into a discriminant standard; the values obtained are used to statistically assign an
unknown to a particular group (e.g. male or female) (Roussas 1997).
As the expression, magnitude and age at initial appearance of sexual dimorphism
varies between populations, sex estimation standards are required to be
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population specific (Franklin et al. 2012a; Lazenby 2002). Standards used to
classify morphometric data according to sex are most accurate when applied to the
population from which they are derived (Lazenby 2002; Burrows et al. 2003). This
is based on evidence that males and females can be more or less dimorphic within
a given population (Franklin et al. 2012b;Walker 2008; SWGANTH 2011).
1.2.1 Sex estimation potential of the metacarpals
Although the pelvis and the skull are considered to be the most sexually dimorphic
bones and therefore preferred for sex estimation, recent research has worked
towards quantifying the sex estimation potential of other bones. For example, it
has been demonstrated that the sternum (Franklin et al. 2012b), femur (Asala et al.
2004), metatarsals (Robling & Ubelaker 1997) and metacarpals (Case & Ross
2007) can be used to correctly classify sex with a high degree of expected accuracy
(above 80%) and they thus have obvious forensic potential. Differential
preservation of remains (or the absence of the pelvis and cranium) can make sex
estimation more difficult. In response to this, this thesis will focus on the sex
estimation potential of the metacarpals of the hands as data can be readily
acquired from radiographs and their exhibited ‘resistance’ to decomposition. Due
to their small tubular structure, metatarsals and metacarpals often exhibit less
postmortem damage at recovery (compared to larger appendicular bones) and are
known to be sexually dimorphic (in particular their interarticular length and
breadth).
Previous research specifically examining the sex estimation potential of the
metacarpals have all reported accuracy rates above 80%; for example; Scheuer and
Elkington 1993 (British population); Falsetti 1995; Stojanowski 1999; Case and
Ross 2007 (American populations); Barrio 2006 (Spanish population); and
Khanpetch et al. 2011 (Thai population). However, Burrows et al. (2003) showed
that the application of skeletal standards based one population to another can lead
to the statistical misclassification of sex. The discriminant function standards from
the previous research of Scheuer and Elkington (1993), Falsetti (1995) and
Stojanowski (1999) were applied to a sample group consisting of modern
American cadavers that had died no more than three years prior to the study
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(Burrows et al. 2003). The accuracy of those standards ranged from 63 to 95%.
The differences in the range of accuracies between the ‘foreign standards’ and the
study conducted by Burrows et al. (2003) can be attributed to population and
temporal differences between the samples used in the different studies. The errors
highlighted by Burrows et al. (2003) have a potentially significant impact on the
admissibility of anthropological evidence.
1.3 Research aims
i) To statistically quantify the accuracy and reliability of two measurement methods of acquiring measurements in digital x-‐rays
Prior to data collection, an intra-‐observer precision test must be conducted to
quantify the accuracy and reliability of using either a landmark or line-‐measure
approach to measure hand bones in digital x-‐rays. The former method requires the
identification of defined landmarks that are then mathematically transformed to
acquire linear inter-‐landmark measurements. In contrast, the latter method only
requires a line to be drawn between two landmarks that provides a direct
measurement value (See Chapter Four for more details). Based on the results of
the intra-‐observer precision test, the method that is the most reliable, accurate and
practical will be used for all subsequent data collection.
ii) To quantify the expression and magnitude of sexual dimorphism in the hand bones (metacarpals and phalanges)
Although the pelvis and cranium are considered to be the most sexually dimorphic
bones, the appendicular skeleton can also be used to estimate sex. Scheuer and
Elkington (1993), Falsetti (1995) and Case and Ross (2007) have all conducted
studies resulting in the production of discriminant functions for estimating sex in
the metacarpals and phalanges that correctly classify sex with up to 87% accuracy.
However Lazenby (2002) and Burrows et al. (2003) demonstrated that
discriminant functions based on one population cannot be applied to ‘foreign’
populations because a loss of accuracy ensues. To this end, the present study will
assess sexual dimorphism in the metacarpals and phalanges of Western Australian
CHAPTER ONE
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individuals. The main aim is to formulate population specific sex estimation
standards for this population, as they do not currently exist.
iii) To statistically quantify the age at which the hand bones are metrically sexually dimorphic
Some sexually dimorphic traits in the size, shape and behaviour of males and
females are evident in the early stages of development. However, the majority of
the differences that occur between the sexes are known to develop under
hormonal influences during puberty (Frayer & Wolpoff 1985). If the latter applies
to the development of the hand bones, one would expect sex specific
morphological differences in the finger bones to manifest at around 14 or 15 years
of age (Schwartz 2007). This study will investigate the minimum age at which sex
can be reliably estimated in the hand bones and, therefore, the age at which
discriminant functions based on a Western Australian population can be
accurately applied in a forensic context.
1.4 Data collection
The sample for the current study consists of 300 antero-‐posterior digital hand x-‐
rays (150 males and 150 females) of adult individuals. These hand x-‐rays are
acquired from the Picture Archiving and Communication Systems (PACS) database,
which contains medical scans from various Western Australian hospitals. A further
sub-‐set of younger individuals are also examined; 100 hand-‐wrist digital x-‐rays of
individuals between the 13 to 18 years of age. Approximately 20 x-‐rays are
acquired for each age group between the ages of 13 and 18 years inclusive; this
sample was used to explore the age at which the metacarpals and phalanges are
quantifiably sexually dimorphic (see above). Only radiographs of hands that show
little (or no) skeletal trauma or anomalies in the metacarpals and proximal
phalanges are used. Additional to these requirements, the selected radiographs
had to clearly show the landmarks that define the required measurements. The
hand x-‐rays obtained from the PACS database are anonymised with only age and
sex data retained. The specific ancestry of each individual is not known, but the
sample is taken as approximating the current Western Australian population. This
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study was approved by the Human Research Ethics Committee of the University of
Western Australia; Project Number RA/4/1/4362.
1.5 Limitations
As with any research, there are limitations with this study that must be taken into
consideration. Firstly, the ancestry of an individual is not recorded when medical
x-‐rays are conducted, as it not a medical requirement. The Western Australian
sample examined in the present study, are thus assumed to be representative of
the current Western Australian population. The Western Australian population
comprises 3.1% indigenous Australians, which is higher than the Australian
average (2.5%). The Australian Bureau of Statistics (Australian Bureau of Statistics
2013) data indicate that 56.2% of the WA population have one or more parent
born overseas and 75% have an ancestry other than Australian (within 2
generations). This compares with Australia as a whole where 46.2% of people have
one or more parent born overseas. In broad terms of ancestry (Australian Bureau
of statistics 2011), the population is predominantly Caucasian in all Australian
states (but not territories).
The second limitation is the effect of skeletal maturation and degeneration; data
collection involves acquiring the maximum length or width measurements of the
hand bones. It is thus required that the digital x-‐rays examined are from
individuals who have reached skeletal maturity which ensures that the hand bones
are of their maximum dimensions and epiphyseal fusion has occurred. As an
individual ages, degenerative bone changes can occur which would also affect the
acquisition of the maximum dimensions of the hand bones (through age-‐related
bone degeneration or loss such as osteopenia or osteoporosis). For the this reason,
the age range of the adult sample was limited to between 18 and 67 years of age,
thus generally ensuring skeletal maturity and the avoidance of degenerative bone
changes. Hand x-‐rays belonging to individuals over 65 years of age were subject to
rigorous scrutiny, to make sure the linear measurements required were
adequately represented.
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1.6 Thesis outline
This study is presented in six chapters, the first being an introduction to the
background of this study and the purpose of this thesis; to develop sex estimation
standards for a Western Australian population based on measurements taken from
the metacarpals. Chapters Two covers the basic anatomy of the hand bones
including anatomical terminology, directionality and muscles associated with the
hand. Chapter Three considers sex estimation methods, and more specifically
previous studies involving sex estimation of hand bones. Chapter Four is the
materials and methods section that outlines the data collection and analysis
protocols. The results of this study and the subsequent discussion and conclusions
are presented in Chapters Five and Six respective
CHAPTER ONE
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CHAPTER TWO
A brief introduction to the anatomy of the hand
2.1 Introduction
The present study concerns with the sex estimation potential of the hand bones
within a Western Australian population; the latter accordingly requires an
understanding of basic hand anatomy. This chapter will outline the skeletal and
muscular components of the hand, in addition to providing an understanding of
terminology used to describe anatomical position, directionality and muscle
movements in that particular region.
2.2 Skeletal anatomy of the hand
The hand is anatomically defined as the terminus of the upper limb, with each
hand consisting of 27 bones (White et al. 2012). These 27 bones are sub-‐divided
into three groups: the wrist or the carpus, the palm or metacarpus, and the fingers
or phalanges (Figure 2.1) (Schwartz 2007; Gray 2010). There are eight carpal (or
wrist) bones that provide the foundation for the five digits of the hand. Two carpal
bones in particular (the scaphoid and lunate) articulate with the radius and form
the wrist joint (Gray 2010).
The next segment of the hand (the metacarpus) comprises five metacarpals within
the palm of the hand; metacarpal 1 (thumb side) through metacarpal 5. The
metacarpals are long tubular bones with a rounded distal articular surface (head)
and a more rigid proximal articular surface (base)(White et al. 2012; Gray 2010).
Each metacarpal can be distinguished by their size and specific morphological
characteristics present in the base of each bone. (White et al. 2012).
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Figure 2.1 Dorsal view of the bones of the right hand: (a) phalanges;
(b) metacarpus; (c) carpus. Source: White et al. 2012
The third and last segment of the hand is made up of the phalanges (fingers). Each
finger has three phalanges; the proximal, medial and distal phalanx (Schwartz
2007; White et al. 2012). The thumb, however, only has a proximal and distal
phalanx (Figure 2.1) (White et al. 2012).
2.3 Anatomical position and directionality
The anatomical position is an orientation of the human body where it is displayed
as standing upright with both feet facing forward and arms are extended along the
sides of the torso with palms facing forward (Ramones 1986). It is this position
that acts as a reference for describing parts of the body in relation to each other, or
in what direction they are facing. For instance if an organ or bone is in front of
another, it is described as anterior (or ventral) that reference point. Table 2.1
below outlines these directional terms.
In describing the hand bones in this study, the thumb (or first digit) is lateral and
the little finger (or fifth digit) is medial, see Figure 2.2. The heads of the
metacarpals and phalanges are the distal ends of the bones; the bases are thus the
proximal ends.
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Table 2.1 Terms used to describe anatomical positioning (Source: Ramones
1986)
Anatomical term Description
Anterior or Ventral In front of
Posterior or Dorsal Behind
Superior or Cranial (towards the head) Above
Inferior or Caudal (towards the tail) Below
Medial Towards the midline
Lateral Further from the midline
Proximal End closest to the head or torso
Distal End furthest from the head or torso
Figure 2. 2 Dorsal view of the left hand with terms used to define the
anatomical position of the hand bones. Source: Bass 2005
Distal
Proximal
Lateral Medial
CHAPTER TWO
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2.4 Muscles acting on the hand
The muscles that act on the hand originate in the forearm and are generally
considered to be a part of either the anterior or posterior compartments of the
forearm (Ramones 1986; Agur & Dalley 2009). Muscle positions are described
according to their origin and insertion, which are the points of attachment of
muscles to bone or fascia. The origin of a muscle is the point from which a muscle
arises and is considered to be the fixed point of attachment with regards to
movement (Gray 2010). Insertion refers to the point at which a muscle ends (or
inserts) and is the point of skeletal movement (Gray 2010).
Muscles allow for several movements along the joints of the upper and lower
limbs, which include flexion, extension, abduction, adduction, pronation and
supination (Gray 2010; Ramones 1986). Flexion is the movement of articulating
bones that acts to decrease the angle between the bones that make up a joint.
Conversely, extension is the movement that increases the angle between the
articulating bones (Gray 2010; Leversedge et al. 2010). Abduction is the lateral
movement of bones away from the mid-‐line and adduction is when a movement
results in moving a body part toward the mid-‐line. Pronation and supination are
rotation movements with pronation used to describe rotation towards the mid-‐line
and supination used to describe rotations away from the midline (Gray 2010; Agur
& Dalley 2009).
The muscles in the anterior compartment of the forearm and the palmar side of the
hand are generally flexors and pronators, whilst the muscles found in the posterior
compartment of the forearm and the dorsal side of the hand are extensors and
supinators (Gray 2010; Cael 2010). The main muscles that act on the hand at both
the carpometacarpal (wrist) and metacarpophalangeal (knuckle) joints are
outlined below.
2.4.1 Anterior compartment of the forearm
The anterior compartment of the forearm consists of muscles that act to flex (or
pronate) the hand at the wrist and the knuckle joint (Cael 2010; Leversedge et al.
2010). There are two layers of muscles in the anterior compartment of the
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13
forearm; superficial and deep. The superficial layer is the layer of muscles closest
to the skin and consists of flexor carpi ulnaris, flexor carpi radialis, flexor digitorum
superficialis, and palmaris longus (Figure 2.3). The muscles in this superficial layer
have a common flexor origin, which is the medial epicondyle of the humerus. The
deep layer of muscles lies beneath the superficial layer and consists of flexor
digitorum profundus and flexor pollicis longus.
Figure 2.3 The most superficial layer of muscles in the anterior
forearm. Source: Agur & Dalley (2009).
Flexor carpi ulnaris is the most medial of the superficial layer of muscles within the
anterior compartment of the forearm (Ramones 1986; Agur & Dalley 2009). This
muscle has two heads that arise from two origins; the humeral head starts from
the medial epicondyle of the humerus and the ulnar head starts from the olecranon
process of the ulna (Cael 2010; Gray 2010). The muscle runs from these two points
of attachment to two of the carpal bones (pisiform and the hook of hamate), as well
as the base of metacarpal five. Flexor carpi ulnaris acts on the hand by allowing
flexion and adduction at the wrist (Cael 2010; Agur & Dalley 2009).
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14
Flexor carpi radialis (like flexor carpi ulnaris) also allows flexion at the wrist joint
and is positioned on the lateral side of the anterior compartment of the forearm
(Cael 2010; Gray 2010; Agur & Dalley 2009). Flexor carpi radialis, however, only
has the one head arising from the medial epicondyle of the humerus and inserts at
the base of metacarpals two and three (Leversedge et al. 2010). As it is located on
the lateral side of the forearm, flexor carpi radialis abducts the hand at the wrist
joint.
Palmaris longus is a muscle found between flexor carpi ulnaris and flexor carpi
radialis that flexes the hand at the wrist joint (Cael 2010). Palmaris longus runs
from the medial epicondyle of the humerus to the flexor retinaculum and palmar
aponeurosis. The flexor retinaculum is a fibrous band (or ligament) that covers the
carpus and the palmar aponeurosis is a layer of fibrous tissue found in the palm of
the hand (Leversedge et al. 2010; Cael 2010; Gray 2010).
Flexor digitorum superficialis (Figure 2.4) also originates from the common flexor
origin and has two additional heads that arise from the coronoid process of the
ulna and the radial tuberosity of the radius (Cael 2010; Leversedge et al. 2010).
Flexor digitorum superficialis inserts into medial phalanges two through five and
allows flexion at the interphalangeal joints and metacarpophalangeal joints of
digits two through five.
Flexor digitorum profundus (Figure 2.5) runs from the medial surface of the
proximal region of the ulna and the interosseous membrane (the fibrous joint
between the ulna and the radius) and inserts at the base of distal phalanges two
through five (Leversedge et al. 2010; Gray 2010). As it inserts at the base of the
distal phalanges, flexor digitorum profundus mainly acts to flex the fingers at the
distal interphalangeal joint. However, the latter muscle also aids in the flexion of
the proximal phalangeal and the metacarpophalangeal joints of the fingers.
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15
Figure 2.4 The second layer of muscle in the anterior forearm. Source:
Agur & Dalley (2009).
Figure 2.5 The third layer of muscle in the anterior forearm. Source:
Agur & Dalley (2009).
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16
Flexor pollicis longus (Figure 2.5) allows flexion of the thumb at the
carpometacarpal, metacarpophalangeal and intercarpal joints (Cael 2010; Gray
2010; Agur & Dalley 2009). Flexor pollicis longus inserts at the anterior surface of
the radius and the interosseous membrane and attaches at the base of the distal
phalanx located in the thumb.
2.4.2 Posterior compartment of the forearm
The muscles in the posterior compartment of the forearm work opposite to those
in the anterior compartment -‐ rather than flex and pronate the posterior forearm
muscles extend and supinate (Gray 2010; Cael 2010; Agur & Dalley 2009). The
muscles are separated into three main groups: the lateral superficial; the medial
superficial; and the deeper muscle groups.
The lateral superficial group consists of extensor carpi radialis longus and extensor
carpi radialis brevis (Figure 2.6). Extensor carpi radialis longus is the longer muscle
and extends from the lateral supracondylar ridge of the humerus to the base of
metacarpal two (Cael 2010). Extensor carpi radialis brevis arises just inferior to the
origin of extensor carpi radialis longus (at the lateral epicondyle of the humerus)
and inserts at the base of metacarpal three (Leversedge et al. 2010; Cael 2010).
Both muscles extend and abduct the hand at the wrist joint.
The medial superficial group of muscles in the posterior compartment of the
forearm includes extensor carpi ulnaris (Figure 2.6), extensor digitorum and
extensor digiti minimi (Figure 2.7). These muscles allow extension of the hand at
the wrist joint, with additional movement specific to their insertions (Ramones
1986). Extensor carpi ulnaris originates in the lateral epicondyle of the humerus
and inserts at the base of metacarpal five. Additional to extension, it also acts to
adduct the hand at the wrist joint (Cael 2010; Agur & Dalley 2009). The lateral
epicondyle is also the origin for extensor digitorum and extensor digiti minimi.
Extensor digitorum inserts at the bases if the middle phalanges and distal
phalanges two through five. It extends the fingers at the metacarpophalangeal,
proximal interphalangeal and distal interphalangeal joints (Cael 2010; Gray 2010).
Extensor digiti minimi inserts at the base of proximal phalanx five and extends the
little finger at both the metacarpophalangeal and interphalangeal joints.
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17
Figure 2.6 The lateral superficial layer of muscles in the posterior
forearm. From left to right: Extensor carpi radialis longus; Extensor carpi
radialis brevis; and Extensor carpi ulnaris. Source: Agur & Dalley (2009).
The final group of muscles in the posterior compartment of the forearm are the
deeper muscles that include extensor indicis, extensor pollicis longus, extensor
pollicis brevis and abductor pollicis longus (Figure 2.8). Extensor indicis runs from
the posterior surface of the ulna and the interosseous membrane and inserts at the
base of proximal phalanx two and extensor indicis extends the index finger (Cael
2010).
Extensor pollicis brevis and longus extend the thumb by inserting at the base of
proximal and distal phalanx one respectively. Both stem from the interosseous
membrane, however extensor pollicis brevis also attaches to the posterior surface
of the radius, and extensor pollicis longus attaches to the posterior surface of the
ulna (Cael 2010; Agur & Dalley 2009). Extensor pollicis brevis has the additional
role of extending (abducting) the thumb.
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18
Figure 2.7 The medial superficial layer of muscles in the posterior
forearm. From left to right: Extensor digiti minimi: Extensor digitorum.
Source: Agur & Dalley (2009).
Abductor pollicis longus further assists extensor pollicis brevis in both the extension
and abduction of the carpometacarpal joint in the thumb. Abductor pollicis longus
originates from the posterior surface of the ulna, radius and interosseous
membrane and insets at the base of metacarpal one (Gray 2010; Cael 2010; Agur &
Dalley 2009).
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19
Figure 2.8 The deep muscle layer of the posterior forearm. From left to
right: Extensor indicis; Extensor pollicis longus; Extensor pollicis brevis;
Abductor pollicis longus; Supinator; and Anconeus. Source: Agur &
Dalley (2009).
2.4.3 Intrinsic muscles of the hand
In addition to the forearm muscles, there are muscles that allow more flexion (or
abduction) of the thumb and little finger. These intrinsic muscles facilitate
specialised movement of the fingers, which in turn allow precision gripping,
grasping and opposition of the thumb (Cael 2010). The intrinsic muscles of the
hand are either hypothenar or thenar muscles; hypothenar muscles acting on the
little finger and thenar muscles acting on the thumb (Ramones 1986; Cael 2010).
The hypothenar muscles include opponens digiti minimi, flexor digiti minimi brevis
and abductor digiti minimi which allow opposition, flexion and abduction of the
little finger (Cael 2010; Gray 2010). The thenar muscles consist of opponens
pollicis, flexor pollicis brevis and abductor pollicis brevis which allow opposition,
flexion and abduction of the thumb (Cael 2010; Agur & Dalley 2009).
20
21
CHAPTER THREE
Sexual dimorphism and sex estimation methods: a review of
previous research
3.1 Introduction
Sex estimation is an integral component in constructing a biological profile from
skeletal tissue and has been extensively researched using both metric and non-‐
metric approaches. This chapter discusses the concept of sexual dimorphism and
the expression of sexual dimorphism in skeletal elements, followed by a review of
literature specifically concerning sex estimation methods based on the analysis of
the fleshed hand and its bones.
3.2 Sexual dimorphism
Sexual dimorphism is the behavioural and physical difference (other than the
reproductive organs and genitalia) that occurs between males and females within
a species (Frayer & Wolpoff 1985; Glücksmann 1981; Park 2013). In general these
differences relate to the size and robusticity of males and females within a species
-‐ in hominid species males generally being larger than females (Krogman 1978;
Park 2013). The extent to which sexual dimorphism is expressed differs between
hominid species, but it can also differ within a species, as the expression and
magnitude of sexual dimorphism is affected by multiple factors including sexual
selection and socio-‐economic role differences (Frayer & Wolpoff 1985).
Human males (like males of most other hominid species) tend to have a larger
overall body size and exhibit greater muscle mass or robusticity (Plavcan 2001).
This size difference is considered to be a secondary sexual characteristic, however,
it is also evident during postnatal growth (Wells 2007). These size differences are
apparent in bones -‐ most obvious in cortical thickness (Wells 2007). Skeletal
dimorphism can be attributed to the difference in the onset and duration of
puberty between males and females. The male pubertal growth spurt tends to
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22
begin 2 years later than the female pubertal growth spurt (Wells 2007). However,
the male pubertal growth spurt lasts longer than their female counterparts, which
results (on average) in males growing more and for longer than females. (Bogin
1999). The latter can result in size sexual dimorphism. Bones exhibiting clear
sexual dimorphism include the pelvis, skull and long bones; these are discussed
below.
3.2.1 The pelvis
The pelvis is potentially the most sexually dimorphic bone in the skeleton and is
therefore the preferred element for sex estimation (Scheuer 2002; Bruzek 2002;
Reichs 1998). Differences in the male and female pelvis are primarily related to
sex-‐specific functional roles; the pelvis has to accommodate both bipedal
locomotion and childbirth in females. This requires a specific morphology, which
in females includes flared iliac blades, a concave sub-‐pubic angle shape, an obtuse
sub-‐pubic angle and a pelvic inlet that is broad mediolaterally (White et al. 2012;
Plavcan 2001; Reichs 1998). Conversely, male pelvis exhibits morphological traits
that are at the opposite end of the spectrum of the features described above.
Differences in male and female pelvic bones are visually quantifiable; a number of
non-‐metric sex estimation methods are available. Phenice (1969) examined the
pelvic bones of 275 adults from the Terry Collection, which consists primarily of
Caucasian American individuals. A classification accuracy of 96% was reported
based on the assessment of three morphological features in the pubis: the ventral
arc: sub-‐pubic cavity: and ischio-‐pubic ramus ridge. Recently, however, the latter
method has yielded poorer classification results, with accuracies ranging from 60
to 80% when applied to a mixed French and Portuguese population (Bruzek 2002).
Such differences in classification accuracies, however, highlights the population
specific nature of these traits and thus the need for local standards.
The other main approach to quantify pelvic sexual dimorphism is the statistical
analysis of linear measurements. Steyn and Işcan (2008) formulated discriminant
sex estimation functions applicable to a modern Greek population; classification
accuracies ranged from 79.7 to 95.9%. Albanese et al. (2003) examined 232
Portuguese and 324 Caucasian American skeletons and produced logistic
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regression equations based on the premise of having only fragments of the pelvis
and femur available for analysis. This resulted in a correct classification accuracy
of 95%, thus reiterating the well-‐known fact that the pelvis is highly sexually
dimorphic.
3.2.2 The skull
Sex estimation methods utilising measurements (or observations) of cranial
features are generally considered accurate due to high levels of size and shape
dimorphism present in the skull. Difference in muscle size and shape between
males and females are attributable to the increased levels of testosterone that
males are exposed to during puberty, which promotes increased muscle mass
(Glücksmann 1981; Braz 2009). Male skulls (on average) exhibit a larger muscle
mass and thus larger attachment sites such as a more prominent glabella (Frontalis
muscle), heavier temporal crests (Temporalis, digastric and occipitalis muscles),
more pronounced nuchal lines (Frontalis, occipitalis, sternocleidomastoid and
trapezius muscles), square-‐shaped mandible (Masseter, mentalis, temporalis and
mylohyoid muscles), a more robust mastoid (Splenius capitis, longissimus capitis
and sternocleidomastoid muscles) and styloid process (Stylohyoid, styloglossus and
stylopharyngeus muscles) and a large zygomatic arch (Masseter, zygomaticus major
and minor muscles) (Gray 2010; White et al 2012).
One of the earliest morphometric sex estimation studies examined Caucasian-‐
American and African American skulls; a total of eight linear measurements
resulted in a classification accuracy of 82 to 89% (Giles & Elliot 1963). Franklin et
al. (2005), when applying a re-‐defined set of measurements based on those of Giles
and Elliot (1963) to a South African population, found that accuracies were slightly
lower at 77-‐80%. Kranioti et al. (2008) examined a Greek population and reported
a classification accuracy of 88.2%. Variation in classification accuracies across
populations is largely due to differences in the expression and magnitude of
sexually dimorphic cranial traits, thus again highlighting the necessity for
population specific standards.
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3.2.3 Long bones
Krogman (1978, pp.143) defines male long bones as “longer and more massive”
than female long bones. Males, as a result of periosteal apposition during puberty,
tend to have long bones with greater articular end and mid-‐shaft diameters, as
well as greater maximum lengths, compared to females. The average size
difference in long bones is evident in a number of forensic anthropological studies.
For example, Krogman (1978) achieved 80% classification accuracy based on
measurements acquired from the femur and humerus. Discriminant function
analyses of humeral epiphyses and femoral epiphyses in a Greek population have
resulted in classification accuracies above 80% (Kranioti et al. 2009; Kranioti et al.
2011). Calculations based on the measurements of maximum head diameter and
base width of the femur resulted in classification accuracies of 85.7 and 84.3%;
these two measurements were considered the most accurate variables of this
study (Kranioti et al. 2011). The latter studies clearly demonstrate high levels of
sexual dimorphism in a variety of long bones.
3.3 Sex estimation based on the analysis of the hand
The following section is an overview of select literature relating to sexual
dimorphism in the hand, as evidenced through the morphometric analysis of the
fleshed hand and its skeletal structure. Published literature based on the analysis
of the fleshed hand is predominantly concerned with the estimation of stature
rather than sex. However, there are a number of anthropometric studies that have
reported sex differences in the dimensions of the palm and hand. Such studies
provide some degree of useful comparative information for the present study.
Thereafter, research based on the analysis of the hand bones is presented
chronologically; progressing from assessing sexual dimorphism in the hand bones
to producing sex estimation standards that are specific to various global
populations.
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25
3.3.1 Fleshed hand
i) Kanchan et al. (2008)
This study examined the relationship between sex and index-‐ring finger ratios in a
South Indian population. A total of 150 male (18 to 51 years of age) and 150 female
(18 to 45 years of age) individuals were examined from the Karnataka coastal
region in South India. The length of the index and ring fingers were measured in
each hand and the index-‐ring finger ratio was calculated.
The results adhere to the general consensus that males are larger than females,
with mean values for both length measurements being significantly larger in the
former sex. There was no evidence of significant bilateral variation. Sex
classification accuracy (left and right hand) in the male sample was 80%; for
females the classification accuracy for the left hand was slightly higher (78%) than
for the right (74%). The results of this study suggest that the index and ring finger
ratio can be used to classify sex; a ratio of 0.97 or less indicative of males and a
ratio more than 0.97 indicative of females.
ii) Kanchan and Rastogi (2009)
The aim of this study was to establish if hand dimensions and indices were
sexually dimorphic in a North and South Indian population. The sample consisted
of 500 students; 120 males and 100 females from a North Indian population, and
110 males and 170 females from a South Indian population. As the effect of
bilateral asymmetry due to hand dominance was not known, only right-‐handed
students were examined. Hand length, hand breadth and palm length were
measured, from which hand and palm indices were calculated; associated
sectioning points were established and their classification accuracy was reported.
In general, the results of this study showed that male hand dimensions were on
average significantly larger than females for both populations. The highest
classification accuracy was 88.7% for males (hand breadth in the left hand) and
91.9% for females (palm length in the left hand). Index values were found to be
less accurate and therefore not applicable for estimating sex in an Indian
population. Only the index value for the left hand in both males and females was
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26
found to be statistically significant. Using the sectioning point based on the hand
indices, the classification accuracies were only 53.9% and 55.9% for males and
females respectively; the latter indices thus have no forensic value.
iii) Kanchan et al. (2010)
This study is a continuation of Kanchan et al. (2008; see above) albeit the methods
are applied to a South Indian adolescent population. The aim was to evaluate if sex
estimation methods using the index-‐ring finger ratio are applicable to sub-‐adults.
The sample consisted of 175 males and 175 females between 13 to 18 years of age.
In the adolescent sample, the index length was not significantly different between
the sexes. However, the difference in ring finger length was highly significant (p≤
0.001) and there were no significant bilateral difference in either sex. Classification
accuracy for males was 83% in the right hand and 82% in the left hand.
Classification accuracy for females was 74% in the right hand and 80% in the left.
The results from this study appear to suggest that the index-‐ring finger ratio
approach to sex estimation could be applied to a sub-‐adult South Indian
population, as the ratio does not appear to fluctuate due to aging or the cessation
of puberty. It is important to note that accuracy rates were not cross-‐validated,
which perhaps suggests that the classification rates are over-‐inflated.
iv) Aboul-‐Hagag et al. (2011)
The aim of this study was to examine sexual dimorphism in the hand of individuals
drawn from an Egyptian population. Data was acquired from a total of 500
students (250 males and 250 females) from Sohag University; the subjects are
stated to be older than 18 years of age. The age range, mean age or maximum age
of the subjects was not provided. Measurements acquired included hand length
and breadth and index finger and ring finger lengths. Hand index and index-‐ring
finger ratios were also calculated.
Hand length, breadth and the hand index were all significantly larger (p≤ 0.05) in
males for both hands. There was no significant bilateral difference in those
measurements. Classification of sex using the hand index resulted in an accuracy of
80% and 81.2% in males for the right and left hands respectively. Classification of
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27
females was 80% for the right and 78% for the left hand. Classification of sex based
on the index-‐ring finger ratios had higher maximum accuracies for both sexes than
the hand index; 90.4% (male right hand) and 85.6% (female right hand). The
results of this study are consistent with previous research; mean male hand
dimensions were significantly greater than the mean dimensions obtained in
females. The results of this study confirm that the hand is sexually dimorphic in an
Egyptian population, however, the discriminant functions were not cross-‐validated
and thus the stated accuracy may be over inflated.
v) Ishak et al. (2012)
Ishak et al. (2012) assessed whether sex could be accurately estimated using
measurements acquired in hands and handprints for a Western Australian
population. The sample comprised 91 males (age range 19-‐68 years) and 110
females (age range 18-‐63 years). Hand breadth, hand length, palm length and the
lengths of the thumb, middle and ring finger were measured in both hands.
Handprints were acquired using a flatbed scanner and the aforementioned
measurements were also taken in the handprints.
All hand and handprint measurements were found to be statistically significantly
different between males and females (p < 0.001). ANOVA F-‐statistic values suggest
that hand breadth, hand length, palm length, handprint breadth and handprint
length express the greatest sexual dimorphism. Univariate functions were
reported to have expected sex classification accuracies of 82.6% to 94.0%; hand
breadth was considered to be the most sexually dimorphic measurement. A cross-‐
validated stepwise discriminant function analysis resulted in a very high
classification accuracy of 96.5%.
It was concluded that within the Western Australian sample, hand length and hand
breadth are more dimorphic than the lengths of the individual fingers; this accords
with previously published literature (ie. Aboul-‐Hagag et al. 2011). The results also
indicate that anthropometric measurements taken in the hand can be used to
accurately estimate sex in a Western Australian population. The study also offers a
“novel” sex estimation method that can be applied to handprints found in a forensic
context (e.g. at a crime scene).
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28
3.3.2 Hand bones
i) Scheuer and Elkington (1993)
These authors suggest that smaller long bones (such as metacarpals, metatarsals
and phalanges) are more likely to be recovered intact than the larger long bones in
appendicular skeleton. Therefore, the aim of this study was to establish if bones of
the hand are sexually dimorphic and to formulate sex estimation standards. The
sample comprised 60 cadavers (of Caucasian British ancestry) from various
medical schools in the United Kingdom. After defleshing, measurements were
taken of all five metacarpals and the first proximal phalanx. There were six
measurements taken and the acquired data were used to calculate an ‘index of
separation’ (male mean value minus the female mean value, divided by the
combined standard deviation). Measurements that resulted in a higher index of
separation were considered to be more dimorphic. Multiple regression analysis
was used to formulate equations, the performance of which were tested on a
relatively small sample (a hold-‐out sample of 20 individuals).
The measurement that had the highest index of separation was the mediolateral
base of metacarpal two (1.41) followed by the mid-‐shaft width of metacarpal one
(1.29). Overall, the mid-‐shaft widths of all the digits (except metacarpal five) had
indices of separation higher when compared to the other measurements
(maximum length, width of the head and width of the base). The top five
classification accuracies of the test sample ranged from 74% (proximal phalanx
one) to 94% (metacarpal one). A multiple regression equation formulated from
the mid-‐shaft width measurements of each hand bone classified sex at 80%
accuracy. The results of this study suggest that in the hand bones measures of
breadth are more likely to exhibit dimorphism than those of length.
ii) Smith (1996)
The aim of this study was to produce sex estimation models for the hand bones. A
total of 120 individuals were sampled; 40 males and 40 females of both Caucasian
American and African American ancestry groups. The age range of the subjects
was 21 to 50 years. The upper age limit of 50 years was implemented in the
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29
attempt to ensure that bones had not undergone degeneration associated with
advanced age. Antero-‐posterior and mediolateral widths of the head, mid-‐shaft and
base of the five metacarpals and 14 phalanges of each hand were measured.
Maximum lengths were also acquired. Significant bilateral differences were found
in measurements taken in the middle phalanges. Stepwise discriminant function
analysis was conducted and eight classification models produced.
The metacarpal models for both hands were the most accurate (87-‐89%), although
there was a large difference in classification accuracies. The metacarpal models
assigned sex correctly at 89% in the left hand, and at 72% in the right. The phalanx
measurements had a sex classification accuracy of >80%. Smith tested the
accuracy of models produced on opposite hands; classification accuracies reached
86% for the metacarpal models, 81% for the distal phalanges, 78% for the
proximal phalanges and 73% for the middle phalanges. This study concluded that
linear measurements acquired from hand bones can be used to accurately classify
both sex and ancestry; with the models derived from metacarpal data achieving
the highest accuracy.
iii) Stojanowski (1999)
Falsetti (1995) followed the methods of Scheuer and Elkington (1993) and applied
it to a North American population. The aim of the study by Stojanowski (1999) was
to build upon the work of Falsetti by applying the same methods to a larger and
‘more contemporary’ sample. A total of approximately 200 subjects from the
Maxwell Museum of Anthropology were examined. The exact sample composition,
however, was not stipulated; Stojanowski estimated maximum sub-‐sample
numbers as 55 Caucasian-‐American males, 22 African-‐American males, 30
Caucasian-‐American females and 15 African-‐American females. The individuals
studied were of European-‐American and African American ancestry born after
1900; the extent to which this sample is considered ‘contemporary’, however, is
debatable. Stojanowski (1999) also proposed models are able to be used in
fragmented or poorly preserved remains.
No significant population differences were found; sex, however, was significantly
different for all dimensions. Seven discriminant functions for each metacarpal
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30
were produced. The highest classification was achieved using measurements of the
articulate ends of the metacarpals (89%) and the lowest classification was found
using combined measurements (maximum length, base length, head length) for
metacarpals two and five (74%). Although the functions produced are unlikely to
be applicable to a ‘modern’ American population, the functions developed by
Stojanowski (1999) provide sex estimation standards that are suitable for
application in fragmented bones and this has potential forensic utility.
iv) Burrows et al. (2003)
The aim of this study was to test previously published standards (e.g. Scheuer and
Elkington (1993), Falsetti (1995) and Stojanowski (1999)) to determine which is
most accurate. The objective was to establish which metacarpal should be used in
preference for sex estimation. A very small sample of 23 individuals of American
ancestry (it is not stipulated whether they were Caucasian or African American)
were classified using measurements taken from the published literature. It is
important to note that the small sample size may have an affect on the statistical
reliability of the results.
Sex classification accuracy achieved using Scheuer and Elkington (1993) and
Falsetti (1995) was 9% and 5% lower than the rates reported by these authors.
The sex classification accuracies achieved using methods from Stojanowski (1999)
were also slightly different; ranging from 65 to 95% rather than 75 to 90%. This
study essentially highlights the need for sex estimation standards to be both
population specific and contemporary in order to avoid inaccuracies in sex
estimation. The sample used by Scheuer and Elkington (1993) was from a different
population and the sample used by Falsetti (1995) came from a different time
period. These are the likely reasons for the differences in the reported sex
classification accuracies.
v) Barrio et al. (2006)
The aim of this study was to produce sex estimation functions applicable to a
Spanish population. Eight bilateral measurements were taken in 697 metacarpals
of 79 adults (37 male and 42 female). The metacarpals were from a skeletal
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31
collection of individuals who had died between 1975 and 1985; the stated age at
death ranged from 20 to 91 years. Univariate discriminant functions were
produced and were cross-‐validated using a leave-‐one-‐out protocol. A total of 120
discriminant functions were produced based on only one measurement each; 40
functions from the right hand, 40 functions from the left, and 40 based on pooled
side data. The function that had the highest classification accuracy was based on
data acquired from the mediolateral diameter of the base of left metacarpal two
(sex classification accuracy of 91%). These results follow the trend that measures
of width and breadth are more sexually dimorphic than measures of length in both
the fleshed and skeletal hand. It was concluded that metacarpal morphometric
data could be used to accurately estimate the sex of Spanish individuals.
vi) Case and Ross (2007)
The aim of this study was to produce discriminant functions for sex estimation
with length as the only variable. The maximum axial length of the metacarpals and
phalanges of both hands were acquired in in a total of 259 subjects (123 females
and 136 males) of Caucasian American or Caucasian European ancestry. The male
sample ranged in age from 18 to 60 years; for the female sample the range was 27
to 72 years.
Sex was estimated more accurately in the left (85.7%) compared to the right
(84.3%) hand. Case and Ross (2007) concluded that discriminant functions based
on length measurements alone could accurately estimate sex and suggested that
lengths be used in preference to transverse measurements. Although previous
literature indicated that transverse measurements are the most dimorphic
dimensions in the hand, Case and Ross suggest that this is likely due to the impact
of functional loading on these dimensions. As length measurements have a
tendency to remain unaffected by functional loading due to “activity-‐variation”
(Case & Ross 2007, pp.269), discriminant functions based on length are less likely
to be affected by population and temporal differences.
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32
vii) El Morsi and Hawary (2012)
The aim of this study was to produce sex estimation predictive models for the hand
bones of individuals from an Egyptian population. A total of 100 Egyptian
individuals (50 male and 50 female) were x-‐rayed and the maximum lengths of the
five metacarpals and 14 phalanges were acquired. Student’s t-‐tests were used to
assess if there was any significant differences between male and female
measurements prior to performing multiple logistic regression analyses. All mean
male measurements were significantly larger than mean female measurements (p
≤ 0.05). A test was also conducted to compare the mean values obtained for the
right and left sides of the pooled sample; the first metacarpal in male subjects was
the only bone reported to have any significant bilateral variance. The bilateral
predictive models derived from the data acquired resulted in correct classification
accuracies of 94% for males and 88% for females. When predictive models of the
right hand alone were used, a classification accuracy of 88% was achieved for both
males and females. The predictive models from the left hand data, however,
correctly classified 90% and 88% of males and females respectively. The
predictive models based on the lengths of the first proximal phalanx, first distal
phalanx, metacarpal three and metacarpal four were the most reliable models for
the estimation of sex in the Egyptian population.
This study confirms that sex can be estimated from length measurements of the
metacarpals and phalanges from individuals of an Egyptian origin. The results
from this study also suggest morphometric data can be accurately acquired in
radiographs. This may be useful in a forensic context whereby both a forensic
anthropologist and forensic pathologists require access to an individual for
examination; x-‐rays are non-‐invasive and would allow for adherent soft tissue to
remain intact, or for skeletal elements to be examined remotely if required.
33
CHAPTER FOUR
Materials and Methods
4.1 Introduction
The primary objective of the present research thesis is to quantify the expression
and magnitude of sexual dimorphism in the metacarpals and phalanges. This
chapter, therefore, accordingly outlines the data collection methods and the
subsequent statistical analyses. The materials studied are digital antero-‐posterior
x-‐rays of the right hand. Validation of the data acquisition methods is also
considered in this chapter.
4.2 Materials
The individuals examined were separated into two sub-‐groups: an adult (300
individuals) and a sub-‐adult (100 individuals) sample. The adult sample comprises
digital hand x-‐rays of 150 males and 150 females; the age range for males was 18.3
to 64.3 years (mean 41.9) and for females was 18.5 to 68.4 years (mean 42.8). The
sub-‐adult sample comprises 100 digital x-‐rays of individuals between 13 and 18
years of age (Table 4.1). The sub-‐adult x-‐rays were sorted into three age groups:
Group A for 12 to 14 years of age; Group B for 14 to 16 years of age; and Group C
for 16 to 18 years of age. The sub-‐adult x-‐rays were grouped into these two-‐year
intervals to allow for more robust statistical analyses of the sub-‐adult data (as
analyses would be conducted on a larger sample than if data was grouped into one
year intervals) and to account for the stages of maturation that can occur at
variable ages between individuals. The sub-‐adult sample is used to quantify the
age at which the hand bones are sexually dimorphic and therefore the youngest
age at which sex estimation discriminant functions can be reliably applied to a
Western Australian population.
The digital hand x-‐rays analysed were acquired from a Picture Archiving and
Communication Systems (PACS) database; this contains medical scans from
various Western Australian hospitals and is maintained by the Department of
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34
Health (DOH). Radiographs of hands that showed little to no skeletal trauma in the
metacarpals and phalanges, and had no obvious anomalies (such as abnormal
osseous growths), were included in the study. Additional to the latter inclusion
requirements, the selected radiographs had to present clear identification of the
landmarks defining the required linear measurements.
Table 4.1 The number individuals in each age group in the sub-‐adult sample.
Age group Sex n
Group A Male 10
(12 – 14 years) Female 11
Group B Male 20
(14 – 16 years) Female 20
Group C Male 20
(16 – 18 years) Female 19
As this study was based on human subjects, approval was required from the
Human Research Ethics Committee (HREC) of the University of Western Australia.
Approval was granted on 11th October 2012 (Project No: RA/4/1/4362) and data
collection commenced thereafter.
4.3 Methods
The two methods evaluated for their suitability for the acquisition of linear
measurements in digital, as well as the definitions of the measurements
subsequently calculated, are outlined below. A precision study was first performed
to assess which of the two available methods for data acquisition provided the
most accurate and reliable data. The statistical approaches for the precision test,
and the subsequent analysis of sexual dimorphism in the hand bones, are outlined
below.
4.3.1 Landmark definitions and typology
i) Landmark definition
Landmarks, in an anatomical context, are “biologically meaningful” (Valeri et al.
1998) points that can be readily identified and are considered homologous
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35
between specimens (O’Higgins 2000; Richtmeier et al. 1995) The acquisition of
landmarks facilitates the analysis of variance in biological forms with landmark
data being “a representation of homologous structures” (Richtmeier et al. 1995,
pp.218). Bookstein (1991) defines three categories of landmarks commonly
recognised within morphometric analyses: Type I; Type II; and Type III.
Type I: These landmarks are considered to be points that can be readily identified
as their location is based on their immediate surroundings that are typically
recognisable anatomical features; such as the point at which different tissues,
structures or bones meet (Bookstein 1991; O’Higgins 2000; Ross & Williams
2008). Examples of Type I landmarks include anatomical features such as cranial
sutures (Coronal suture, Bregma, etc.) and blood vessel branches (Aorta) or
foramina (Foramen magnum) (Bookstein 1991; Valeri et al. 1998). Type I
landmarks are reproducible because they represent anatomical features that are
normally considered to be the same between specimens; for example, if the
bregma (the junction of the sagittal and coronal sutures) is used as a landmark,
then it must follow the same definition between all specimens in the study
(Cramon-‐Taubadel et al. 2007; O’Higgins 2000).
Type II: Type II and Type III landmarks tend to be more ambiguous to locate and
identify than Type I landmarks (Cramon-‐Taubadel et al. 2007). The Type II
landmarks category is the intermediate category, consisting of anatomical points
that are homologous between specimens based on their geometric relationship
with their immediate surroundings (Bookstein 1991; Ross & Williams 2008).
Bookstein (1991) refers to Type II landmarks as “maxima of curvature of other
local morphometric processes” (pp.64) and such landmarks include, for example,
points of muscle attachment (O’Higgins 2000; Ross & Williams 2008).
Type III: These landmarks are “extremal points” (Bookstein 1991, pp.65) that
points are most likely to be endpoints of an overall distance, or a point that is
defined as furthest away from another (Bookstein 1991; O’Higgins 2000). Type III
landmarks have at least one coordinate that is inconsistent (Bookstein 1991). This
means that the location of a landmark can, at most, be narrowed down to a border,
surface or end point; the landmark is therefore less likely to be reproducible or
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36
remain consistent between specimens (Valeri et al. 1998; Slice et al. 2004). The
medial point of an epiphysis, an end point of a diameter or location of a fissure are
all examples of Type III landmarks.
In the present study a total of 80 landmarks were acquired in each digital hand x-‐
ray; eight landmarks in each of the five metacarpals and five proximal phalanges.
The definitions of those landmarks are based on previously published papers – see
Figure 4.1 and Table 4.2, which outlines the landmarks acquired using metacarpal
two as an example. The landmarks acquired in this study are predominately Type
III landmarks (Table 4.2), which gives reason to expect relatively lower intra-‐
observer accordance and measurement accuracy. However, a precision test was
conducted prior to data acquisition in order to statistically quantify the accuracy
and reliability of landmark acquisition – see Section 4.5 below.
Figure 4.1 Antero-‐posterior view of metacarpal two, metacarpal one
and proximal phalanx one (from left to right) illustrating the eight
landmarks defined in Table 4.2.
4.3.2 Measurement definitions
The linear measurements acquired in this study largely follow established
definitions (Scheuer & Elkington 1993; Case & Ross 2007) and any modifications
are accordingly noted. There are four measurements taken in each of the five
metacarpals and proximal phalanges; each measurement corresponds to the linear
MDMC1
MPMC1
MHMC1 LHMC1
MBMC1 LBMC1
MSMC1 LSMC1
MDPP1
MHPP1
MPPP1
MBPP1
MSPP1
LHPP1
LBPP1
LSPP1
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37
distance between two pre-‐determined landmarks. Figure 4.2 and Table 4.3 outline
the measurements acquired using metacarpal two as an example.
Table 4.2 Definitions of the landmarks acquired for metacarpal two
Landmark Name Code Description
Most distal point of metacarpal twoi, ii
MDMC2 The point of metacarpal two that is furthest from the carpus when the hand is in anatomical position.
Most proximal point of metacarpal twoi, ii
MPMC2 The point of metacarpal two that is closest to the carpus when the hand is in anatomical position.
Most medial point of the head of metacarpal twoi, ii, iii
MHMC2 The point of the head that is closest to the 5th digit or mid-‐line of the body when the hand is in anatomical position.
Most lateral point of the head of metacarpal twoi, ii, iii
LHMC2 The point of the head that is on the side on the thumb side of the bone or furthest from the mid-‐line of the body when the hand is in anatomical position.
Most medial point of the base of metacarpal twoi, ii, iii
MBMC2 The point of the base that is on the side on the little finger side of the bone or closest the mid-‐line of the body when the hand is in anatomical position.
Most lateral point of the base of metacarpal twoi, ii, iii
LBMC2 The point of the base that is on the side on the thumb side of the bone or furthest from the mid-‐line of the body when the hand is in anatomical position.
Most medial point of the mid-‐shaft region of metacarpal twoi, ii, iii, iv
MSMC2 Point in the mid-‐shaft region that is on the side on the little finger side of the bone or closest the mid-‐line of the body when the hand is in anatomical position.
Most lateral point of the mid-‐shaft region of metacarpal twoi, ii, iii, iv
LSMC2 Point in the mid-‐shaft region that is on the side on the thumb side of the bone or furthest from the mid-‐line of the body when the hand is in anatomical position.
Key: i. Falsetti, 1995; ii. Smith, 1996; iii. Scheuer & Elkington, 1993; iv. Lazenby, 1994.
4.3.3 Measurement acquisition – OsiriX®
The medical image processing software OsiriX® offers a number of different
approaches to measurement acquisition; the validity of two approaches were
tested.
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38
Figure 4.2 Antero-‐posterior view of metacarpal two illustrating the
four measurements (See Table 4.3 for definitions)
Table 4.3 Definitions of acquired measurements for metacarpal two
Measurement name Code Definition #Landmarks
Maximum length of metacarpal twoi, ii, iii
MLMC2
The maximum linear distance between the most distal point of the bone to the most proximal point of the bone.
MPMC2 -‐ MDMC2
Mediolateral head width of metacarpal twoii, iii, iv, v
WHMC2
The maximum linear distance between the most medial point and the most lateral point of the head of the bone.
MHMC2 -‐ LHMC2
Mediolateral base width of metacarpal twoii, iii, iv, v
WBMC2
The maximum linear distance between the most medial point and the most lateral point of the base of the bone.
MBMC2 -‐ LBMC2
Mediolateral mid-‐shaft width of metacarpal twoii, iii, iv, v
WMMC2 The maximum linear distance between the most medial and most lateral point of the mid-‐shaft region.
MSMC2 -‐ LSMC2
Key: i. Case & Ross, 2007; ii. Falsetti, 1995; iii. Smith, 1996; iv. Scheuer & Elkington, 1993; v.
Lazenby, 1994. # Landmarks defined in Table 4.2
MLMC2
WHMC2
WMMC2
WBMC2
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39
i) Landmark acquisition
The landmark method involves identifying and recording the three-‐dimensional
(3D -‐ x, y, z) coordinates of landmarks that define a particular measurement in the
digital hand x-‐rays. The 3D coordinates of each landmark is exported from OsiriX®
(in a ‘csv’ format) into MorphDB which is a program used to calculate linear inter-‐
landmark distances. MorphDB is a Centre for Forensic Science (UWA) developed
programme that calculates linear measurements from x, y, z coordinate data
exported from OsiriX® and also produces data files suitable for direct import into
the Statistical Package for the Social Sciences (SPSS) software.
For example, with reference to metacarpal two, maximum length (MLMC2) is
defined as the distance between the most distal and proximal points (MDMC2 to
MPMC2). In this instance, MorphDB would calculate the inter-‐landmark distance
between the 3D coordinates of the MDMC2 and MPMC2 landmarks resulting in a
value for MLMC2. The landmark method required 80 landmarks to be located,
labelled and imported into MorphDB for each digital hand x-‐rays.
ii) Measurement acquisition
The line-‐tool method is a standard inclusion in the software (OsiriX®) that allows
direct measurements in any medical modality. A line is drawn between the
landmarks that define any measurement; the position of either landmark can be
moved medio-‐laterally to find the maximum length or in a proximal/distal
direction for a maximum width. The line-‐tool method was used to directly acquire
a total of 40 measurements in each digital hand x-‐ray.
4.4 Statistical analyses: precision test
Prior to data collection a precision study was performed to statistically quantify
the intra-‐observer error and thus determine data quality. In general there are two
main sources of measurement error; human error or “intra-‐individual variation”
(Liu 1988) and error resulting from inaccurate measuring equipment (Liu 1988;
Goto & Mascie-‐Taylor 2007). It is important to conduct a precision study prior to
data collection, as sources of error need to be quantified. High percentages of
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40
measurement error can affect statistical validity, as variation may be more
representative of measurement error rather than the genetic and environmental
factors it is meant to represent (Weinberg et al. 2005; Franklin et al. 2012a). A
precision study also allows for measurements to be re-‐defined, or methods of data
collection to be altered, if they are found to be inaccurate and unreliable.
To quantify measurement error, six randomly selected hand x-‐rays were measured
a total of six times each, with a minimum of 1 day between repeats to minimise
data recall. As there is a potential for the current study to produce population
specific standards that can be used for further forensic applications, the precision
test was practiced with caution. A six by six precision test format was chosen to
ensure statistics quantifying intra-‐observer error were based on reliable data.
Measurements were acquired using both measurement methods (see above); the
technical error of measurement (TEM), the relative technical error of
measurement (rTEM) and the coefficient of reliability (R) were then calculated.
These statistics are accordingly defined below.
i) Technical error of measurement
The technical error measurement (TEM) provides a measure of “the magnitude of
error” (Weinberg et al. 2005, pp.369) and is presented in the units of the original
measurement. This is used to estimate any intra-‐ or inter-‐observer precision by
measuring the standard deviation between repeated measurements (Goto &
Mascie-‐Taylor 2007). The TEM calculated by considering the difference between
the measurements taken along with the number of measurements and the number
replicates. TEM is considered to be an “accuracy index” (Goto & Mascie-‐Taylor
2007, pp.254) and is an indication of how much variation in a trait can be
attributed to observer error, rather than genetic or environmental factors. The
𝑇𝐸𝑀 is calculated as:
TEM = √(∑D)2
xN
Key: D: difference between measurements
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41
N: number of replicates
x : number of measurements taken or number of subjects
ii) Relative technical of error of measurement
The relative technical error of measurement is a standardisation of the TEM where
the TEM is expressed as a percentage (Goto & Mascie-‐Taylor 2007; Arroyo et al.
2010). This allows comparison between measurements of a different size, as TEM
is positively related to measurement size; e.g. larger measurements (such as
maximum length) having a larger TEM. Previous studies (e.g. Ulijaszek & Kerr
1999; Goto & Mascie-‐Taylor 2007) have suggested that an rTEM value higher than
5% is an indicator of “imprecise” data collection. The formula for the calculation of
rTEM is:
rTEM = TEM
x100 VAV
Key: VAV: variable average value
iii) Coefficient of reliability
The coefficient of reliability is an estimation of how much variation is not
attributable to measurement error (Weinberg et al. 2005). The value of ‘R’ ranges
from 0 to 1; a value of 0 (or closer to 0) would suggest that any between subject
measurement variation is most likely due to measurement error (Marks et al.
1989). A value of 1 (or close to 1), therefore, indicates that any variation found
between subjects is not present due to measurement error (Marks et al. 1989). For
example, an ‘R’ of 0.95 suggests that 95% of any variation is a result of genetic or
environmental factors rather than observer error. This leaves 5% variation
accounted for by observer (or measurement) error, thus suggesting that only 5%
of measurement variation is due to imprecision. Ulijaszek and Kerr (1999) suggest
that a coefficient of reliability of 0.9 (or higher) is required for data to be
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42
considered accurate and reliable (Weinberg et al. 2005; Franklin et al. 2012a;
Marks et al. 1989).
The coefficient of reliability formula is:
R = total TEM2
SD2
Key: SD2 – population variation of the trait that was measured.
4.5 Statistical analyses: measurement data
Prior to subsequent statistical analyses, descriptive statistics such as the mean,
standard deviation and range are first calculated. Normality was also tested using
the Shapiro-‐Wilk test, which is discussed below. Further statistical analyses were
conducted to assess the significance of difference in measurement data between
males and females, as well as the relationship between sex and the linear
measurements. All statistical analyses were performed using the Statistical Package
for the Social Sciences (SPSS) version 19.0.
4.5.1 Normality tests
In order to perform analyses such as an ANOVA or discriminant function analysis,
it is recommended that the data are normally distributed. The SPSS software offers
two tests of normality; the Kolmogorov-‐Smirnov and Shapiro-‐Wilk tests. Both are
applicable to the data acquired, however, the Shapiro-‐Wilk test is considered to be
more robust for data sets with less than 2000 samples. It is for the latter reason
that this test was used instead of the Kolmogorov-‐Smirnov statistic (Shapiro, Wilk
& Chen 1968). The Shapiro-‐Wilk statistic standardises the test data and compares
it to a normal distribution. The variance between the two distributions is reported,
along with a p-‐value indicating statistical significance. The Shapiro-‐Wilk test
assumes that the data is from a normal distribution as its null hypothesis.
Therefore, if the p-‐value reported is statistically significant (p<0.05), the null
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43
hypothesis is rejected, and that measurement violates assumptions of a normal
distribution.
4.5.2 Significance tests
i) Independent sample t-‐test
An independent sample t-‐test is used to assess the differences in the means of a
dependent variable between two samples from different populations. For this
particular study, the mean hand bone measurements acquired from the males and
females sampled from the Western Australian population are compared to the
mean measurements acquired from five foreign populations. In addition, the mean
hand bone measurements of males and females within the same population are
also compared using a t-‐test and the magnitude of differences is compared
between five comparative populations. As the comparison is performed using data
from previously published papers, independent t-‐tests will be calculated using the
mean, standard deviation and n values (sample size) as the raw measurement data
is not presented in the published literature.
The null hypothesis is that there is no significant difference between the two
sample means and any variance is due to factors other than the independent
variable (sex) (Lucy 2005; Townend 2003). The alternate hypothesis, therefore, is
that there is a significant difference between sample means (hand bone
measurements) and the variance may be due to a sex difference. From a t-‐test a p-‐
value is obtained which indicates the likelihood the means of the samples vary due
factors other than the independent variable; i.e. chance or measurement error
(Madrigal 2012; Lucy 2005). A p-‐value greater than 0.05 suggests that there is no
significant difference between the samples, as the evident variance is likely related
to factors other than sex 5% of the time or higher (Madrigal 2012; Townend 2003).
A p-‐value of less than 0.05 is associated with a significant difference between two
populations.
ii) Analysis of variance (ANOVA)
An ANOVA, like an independent sample t-‐test, compares the means of two samples
to determine if there is a significant difference (DeVeaux et al. 2012; Madrigal
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44
2012). The ANOVA expresses the dispersion of sample means around the mean of
all observations (e.g. males and females combined, or the total data set.) (Lucy
2005). An ANOVA, however, generally provides a more robust statistical analysis
than an independent sample t-‐test, due to an additional statistics -‐ the F-‐ratio. The
F-‐ratio expresses the dependence of a variable on the factors the study is based on
(Madrigal 2012). For this study, the F-‐ratio would indicate how dependent the
variance in measurement data between the male and female sample is on the sex
difference between the groups. The F-‐ratio is calculated by comparing the variance
within a sample with the variance between the samples (Madrigal 2012). The
equation is as follows;
F = between sample variance within sample variance
A high F-‐value thus suggests that the ‘between sample’ variance is greater than the
‘within sample’ variance. A p-‐value is also calculated and is used to assess whether
the variance between means (and thus the high F-‐score) is likely to have occurred
due to error or an independent variable (Ramsey & Schafer 2002). F-‐ratios also
allow for the identification of measurements that are more likely to express sexual
dimorphism (Franklin et al. 2008). This assists in interpreting which
measurements of the hand bones are likely to be the most accurate for estimating
sex.
In the present study, a one-‐way ANOVA is used with sex as the dependent variable
and the hand bone measurements as the independent variables. The null
hypothesis of the one-‐way ANOVA model is that sample means are identical and
imply that there is no significant difference between male and female
measurement values (Lucy 2005).
4.5.3 Discriminant function analyses
Discriminant function analysis (DFA) involves establishing a function that includes
a combination of variables for discriminating between two (or more) groups
(Agresti 2002; Slaus & Tomicic 2005; Pietrusewsky 2008). A DFA allows for the
formulation of a prediction model that, in reference to the present study, facilitates
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45
sex estimation based on hand bones (Patriquin et al. 2005; Slaus & Tomicic 2005).
This statistic allocates group membership and also provides an indication of the
strength of a relationship that a dependent variable has with the independent
variable; the variables most likely to accurately predict group membership are
more heavily weighted in the discriminant function (e.g. higher unstandardized
coefficient values) (Işcan et al.1998).
The discriminant scores produced from a discriminant function are classified
based on their relationship to a sectioning point. The sectioning point of this study,
as per previously published studies, is established as a value that is halfway
between the male and female mean scores (Slaus & Tomicic 2005). If the
discriminant score is lower than the sectioning point, the discriminant score is
likely to represent a female individual (Agresti 2002). Two DFA approaches were
applied and cross-‐validation for both methods was conducted to ensure the
validity of the predictive models produced. The cross-‐validation gives an estimate
of how accurately a function will allocate group membership by testing the model
on a variable that was leave out of the sample during the discriminant function
analysis (Agresti 2002; Patriquin et al. 2005). Posterior probabilities are calculated
to also assess how accurate and effective a predictive model is in classifying
variables. A score is given between 0 and 1, with scores closer to one suggesting
that a variable is further away from the sectioning point than variables with scores
closer to 0. If a variable is further from the sectioning point, the associated function
the likelihood of classification due to chance decreases. This renders the function
effective.
i) Direct discriminant function analysis
Direct DFA is the production of a predictive model based on the individual needs of
the user, with variables in the discriminant function manually selected. Direct DFA
would be considered in situations such as those published by Stojanowski (1999),
who formulated seven discriminant functions designed for the application in
metacarpals in different stages of preservation. Direct DFA essentially allows for
the manipulation of a predictive model based on what data is available. The
predictive models used as a result of direct DFA are not necessarily the most
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46
accurate; this is because the variables inputted may not be the most accurate
predictors of group membership. In some instances, a discriminant function using
only one variable is required and with these cases a demarking point is calculated
(Patriquin et al. 2005). The demarking point is essentially the sectioning point for
the discriminant scores using the single variable discriminant function and is the
halfway point between the combined male and female mean measurement value
for that variable (Franklin et al. 2008).
ii) Stepwise discriminant function analysis
Stepwise DFA is a method where the discriminant function is generated
sequentially through a method of variable selection or elimination (Ramsey &
Schafer 2002; Agresti 2002). A stepwise DFA generally results in functions that
provide the highest classification accuracy as the independent variables with the
highest F-‐vales are selected (Işcan et al. 1998). Inclusion of variables in the
predictive model is based on the Wilk’s lambda statistic; this is a measure of how
much variance in discriminant scores cannot be attributed to the differences that
exist between the groups considered (Ramsey & Schafer 2002; Agresti 2002). A
lower Wilk’s lambda value would, therefore, suggest that there is a lower
percentage of variance that can be explained by something other than the
difference between groups. Independent variables that result in a lower Wilk’s
lambda value are included in the predictive model due to their existing
relationship with the dependent variable. A low Wilk’s lambda value, however,
does not necessarily suggest that a predictive model has high classification
accuracy (Ramsey & Schafer 2002). Rather, the classification accuracy of
discriminant functions developed will be calculated as the percentage of subjects
from the data sample that can be correctly classified using the developed
discriminant functions.
iii) Testing of foreign discriminant function analyses
Previously published predictive models based on populations foreign to Western
Australia were applied to the Western Australian data acquired. This was to
further establish the need for population specific sex estimations standards. From
each of the comparative populations chosen, the function that had the highest
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47
classification accuracy and measurements in common with the current study was
used to classify the individual sample.
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48
49
CHAPTER FIVE
Results
5.1 Introduction
This chapter outlines the results from each of the statistical analyses conducted in
this study, including the precision test, comparison of mean male and female data,
the assessment of population differences, and the results of the various
discriminant function analyses. The dataset used in this study consisted of two
groups; adults (150 males and 150 females) and sub-‐adults (50 males and 50
females). The groups were analysed separately in order to fulfil the required aims
of the study (see Chapter One). The results from the precision test are presented
first, followed by the results from the analysis of the adult, and then the sub-‐adult,
data.
5.2 Measurement precision
Two measurement methods (landmark and line-‐tool -‐ see Chapter Four) were
evaluated prior to data acquisition to assess which produced the most accurate
and reliable data. Measurement precision was quantified using the technical and
relative technical error of measurement (TEM; rTEM) and the coefficient of
reliability (R) (Table 5.1 and Table 5.2).
i) Landmark method
The results from the precision test for the landmark method are shown in Table
5,1. The rTEM values ranged from 0.49% (maximum length of metacarpal three) to
3.26% (maximum mid-‐shaft width of proximal phalanx one). The mean rTEM was
1.77%. The lowest R-‐value was 0.96 for the maximum mid-‐shaft width of proximal
phalanx one. The highest R-‐value of 1.00 was shared by 12 measurements (Table
5.1). The mean R-‐value for measurements acquired using the landmark method
was 0.99.
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50
Table 5.1 Measurement precision (TEM, rTEM and R) for the landmark measurement method. Measurement TEM R rTEM MC1 Maximum Length (MLMC1) 3.05 1.00 0.76 MC1 Mediolateral Width Head (WHMC1) 2.20 0.99 1.70 MC1 Mediolateral Width Base (WBMC1) 3.07 0.99 2.31 MC1 Maximum Mid-‐Shaft Width (WMMC1) 1.97 0.99 2.42 MC2 Maximum length (MLMC2) 3.16 1.00 0.51 MC2 Mediolateral Width Head (WHMC2) 3.18 0.99 2.43 MC2 Mediolateral Width Base (WBMC2) 4.19 0.98 2.61 MC2 Maximum Mid-‐shaft Width (WMMC2) 2.01 0.98 2.58 MC3 Maximum length (MLMC3) 2.84 1.00 0.49 MC3 Mediolateral Width Head (WHMC3) 2.53 0.99 1.86 MC3 Mediolateral Width Base (WBMC3) 3.23 0.98 2.66 MC3 Maximum Mid-‐shaft Width (WMMC3) 1.09 0.99 1.47 MC4 Maximum length (MLMC4) 3.59 1.00 0.70 MC4 Mediolateral Width Head (WHMC4) 2.95 0.99 2.50 MC4 Mediolateral Width Base (WBMC4) 2.62 0.99 2.37 MC4 Maximum Mid-‐shaft Width (WMMC4) 1.34 0.99 2.21 MC5 Maximum length (MLMC5) 3.62 1.00 0.77 MC5 Mediolateral Width Head (WHMC5) 1.89 0.99 1.61 MC5 Mediolateral Width Base (WBMC5) 3.08 0.97 2.59 MC5 Maximum Mid-‐shaft Width (WMMC5) 1.74 0.98 2.55 PP1 Maximum Length (MLPP1) 2.16 1.00 0.77 PP1 Mediolateral Width Head (WHPP1) 2.21 0.98 2.27 PP1 Mediolateral Width Base (WBPP1) 2.84 0.98 2.29 PP1 Maximum Mid-‐shaft Width (WMPP1) 2.14 0.96 3.26 PP2 Maximum Length (MLPP2) 2.33 1.00 0.64 PP2 Mediolateral Width Head (WHPP2) 2.08 0.98 2.17 PP2 Mediolateral Width Base (WBPP2) 1.62 1.00 1.15 PP2 Maximum Mid-‐shaft Width (WMPP2) 1.59 0.99 1.99 PP3 Maximum Length (MLPP3) 2.87 1.00 0.71 PP3 Mediolateral Width Head (WHPP3) 2.54 0.98 2.42 PP3 Mediolateral Width Base (WBPP3) 1.77 1.00 1.28 PP3 Maximum Mid-‐shaft Width (WMPP3) 1.52 0.99 1.84 PP4 Maximum Length (MLPP4) 2.23 1.00 0.58 PP4 Mediolateral Width Head (WHPP4) 1.33 1.00 1.34 PP4 Mediolateral Width Base (WBPP4) 1.77 0.99 1.36 PP4 Maximum Mid-‐shaft Width (WMPP4) 1.52 0.99 1.95 PP5 Maximum Length (MLPP5) 1.95 1.00 0.65 PP5 Mediolateral Width Head (WHPP5) 2.08 0.98 2.53 PP5 Mediolateral Width Base (WBPP5) 2.31 0.99 1.87 PP5 Maximum Mid-‐shaft Width (WMPP5) 1.67 0.98 2.53
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Table 5.2 Measurement precision (TEM, rTEM and R) for the line-‐tool measurement method. Measurement TEM R rTEM MC1 Maximum Length (MLMC1) 2.54 1.00 0.63 MC1 Mediolateral Width Head (WHMC1) 2.48 0.99 1.87 MC1 Mediolateral Width Base (WBMC1) 1.36 1.00 1.02 MC1 Maximum Mid-‐Shaft Width (WMMC1) 1.44 0.99 1.81 MC2 Maximum length (MLMC2) 1.94 1.00 0.31 MC2 Mediolateral Width Head (WHMC2) 2.30 0.99 1.73 MC2 Mediolateral Width Base (WBMC2) 2.08 1.00 1.29 MC2 Maximum Mid-‐shaft Width (WMMC2) 2.11 0.98 2.79 MC3 Maximum length (MLMC3) 1.40 1.00 0.24 MC3 Mediolateral Width Head (WHMC3) 1.95 1.00 1.41 MC3 Mediolateral Width Base (WBMC3) 2.99 0.98 2.40 MC3 Maximum Mid-‐shaft Width (WMMC3) 2.48 0.97 3.34 MC4 Maximum length (MLMC4) 1.96 1.00 0.38 MC4 Mediolateral Width Head (WHMC4) 1.35 1.00 1.11 MC4 Mediolateral Width Base (WBMC4) 2.34 0.99 2.02 MC4 Maximum Mid-‐shaft Width (WMMC4) 0.92 0.99 1.54 MC5 Maximum length (MLMC5) 2.45 1.00 0.52 MC5 Mediolateral Width Head (WHMC5) 1.06 1.00 0.89 MC5 Mediolateral Width Base (WBMC5) 1.37 0.99 1.14 MC5 Maximum Mid-‐shaft Width (WMMC5) 1.47 0.98 2.12 PP1 Maximum Length (MLPP1) 1.38 1.00 0.49 PP1 Mediolateral Width Head (WHPP1) 1.55 0.99 1.57 PP1 Mediolateral Width Base (WBPP1) 1.55 0.99 1.23 PP1 Maximum Mid-‐shaft Width (WMPP1) 1.67 0.98 2.59 PP2 Maximum Length (MLPP2) 1.37 1.00 0.38 PP2 Mediolateral Width Head (WHPP2) 1.60 0.99 1.61 PP2 Mediolateral Width Base (WBPP2) 1.17 1.00 0.82 PP2 Maximum Mid-‐shaft Width (WMPP2) 0.98 1.00 1.24 PP3 Maximum Length (MLPP3) 1.67 1.00 0.41 PP3 Mediolateral Width Head (WHPP3) 1.60 0.99 1.48 PP3 Mediolateral Width Base (WBPP3) 1.07 1.00 0.76 PP3 Maximum Mid-‐shaft Width (WMPP3) 1.10 1.00 1.33 PP4 Maximum Length (MLPP4) 1.26 1.00 0.33 PP4 Mediolateral Width Head (WHPP4) 1.48 0.99 1.46 PP4 Mediolateral Width Base (WBPP4) 1.34 1.00 1.02 PP4 Maximum Mid-‐shaft Width (WMPP4) 1.07 1.00 1.39 PP5 Maximum Length (MLPP5) 1.26 1.00 0.42 PP5 Mediolateral Width Head (WHPP5) 1.94 0.98 2.33 PP5 Mediolateral Width Base (WBPP5) 1.38 1.00 1.12 PP5 Maximum Mid-‐shaft Width (WMPP5) 1.81 0.98 2.75
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ii) Line-‐tool method
The results of the precision test for the line-‐tool method are shown in Table 5.2.
The lowest rTEM (0.24%) was for the maximum length of metacarpal three. The
highest rTEM (3.34%) was for the maximum mid-‐shaft width of metacarpal four.
The mean rTEM was 1.33%. The R-‐values for the line-‐tool method measurements
from 0.97 (maximum mid-‐shaft width of metacarpal three) to 1.00; the highest R-‐
value is shared by 20 measurements (Table 5.2).
iii) Summary
Both measurement methods yielded results with rTEM values on average much
less than 5% and R-‐values that were equal (or close) to 1. Overall, the line-‐tool
method is the most precise and reproducible of the two methods examined (lower
mean rTEM and higher R-‐values). For this reason, subsequent data collection
conducted was performed using the line-‐tool measurement method.
5.3 Descriptive statistics for the adult data
5.3.1 Age distribution
The mean age, standard deviation and range for the male and female individuals
are shown in Table 5.3. The adult males ranged from 18.34 to 64.34 years of age
(mean 41.94 years). The age range for the adult females was from 18.00 to 68.36
(mean 42.26 years).
Table 5.3 Distribution of age (in years) of the adult Western Australian sample.
Sex n Range Mean Standard Deviation
Male 150 18.34 – 64.34 41.94 14.11
Female 150 18.00 – 68.36 42.26 14.19
5.3.2 Measurement Normality
Measurement normality was tested using the Shapiro-‐Wilk method; the data is
standardised and compared to a normal distribution. Of the 40 measurements
acquired in the male sample, a total of 37 were normally distributed. The three
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male measurements that violate assumptions of normality are the base width of
metacarpal one, base width of metacarpal three and the head width of metacarpal
five. For the female sample, a total of two measurements were not normally
distributed; the base width of metacarpal one and, the head width of proximal
phalanx two.
Inspection of the raw data for these five measurements indicated no outliers
outside of three standard deviations of the mean. As ANOVA and discriminant
function analyses are relatively robust to violations of normality, the five
measurements were retained (Ramsey and Schafer 2002; DeVeaux et al. 2012).
Subsequent analyses performed using these measurements were duly scrutinised
to ensure their robustness to prevent potentially erroneous results.
5.3.3 Univariate comparisons
The descriptive statistics for the adult hand bone measurements are presented in
Table 5.4. Overall, the mean male values were larger than those of the female
individuals for all measurements. The maximum length of metacarpal three had
the largest mean sex difference (5.77 mm) and maximum mid-‐shaft width of
metacarpal three had the smallest mean sex difference (1.07 mm). In general the
maximum length and base width measurements had larger mean differences
between the sexes, compared to the head and mid-‐shaft width measurements
(Table 5.4).
To assess the extent of morphometric sexual dimorphism, an ANOVA was
conducted to compare the adult male and female data. All measurements were
statistically significantly different (Table 5.4). The most sexually dimorphic
measurement was the base width of proximal phalanx two (F=363.88; p<0.001).
The least sexually dimorphic measurement was the maximum length of metacarpal
five (F=61.35; P<0.001). Sex differences explain 17 – 55% of sample variance.
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Table 5.4 Descriptive statistics and means comparison of mean hand bone measurements (in mm).
Measurement a Male (n = 150) Female (n=150) F R-‐square p-‐value
Mean SD Range Mean SD Range MLMC1 48.86 3.21 40.50 – 57.81 44.6 2.88 36.72 – 51.90 146.13 0.33 *** WHMC1 17.03 1.41 12.97 – 20.73 14.92 1.11 11.81 – 17.64 207.59 0.32 *** WBMC1 16.61 1.6 13.76 – 21.77 14.7 1.2 12.69 – 18.14 137.31 0.41 *** WMMC1 9.91 1 7.38 – 13.03 8.78 0.76 6.83 – 10.81 121.6 0.29 *** MLMC2 74.75 4.55 62.66 – 88.17 68.98 3.96 60.42 – 78.40 137.62 0.32 *** WHMC2 21.09 1.58 14.11 – 20.23 18.55 1.27 11.93 – 17.98 234.42 0.33 *** WBMC2 17.12 1.35 17.56 – 25.36 15.32 1.2 15.09 – 22.03 147.63 0.44 *** WMMC2 9.45 0.82 7.68 – 11.89 8.23 0.7 6.64 – 10.46 191.69 0.39 *** MLMC3 69.16 4.4 57.26 – 82.90 63.83 3.65 55.37 – 74.86 130.23 0.3 *** WHMC3 15.83 1.35 14.38 – 21.27 13.98 1.18 11.20 – 17.11 160.04 0.39 *** WBMC3 17.38 1.32 13.52 – 20.06 15.4 1.17 12.39 – 18.56 189.27 0.35 *** WMMC3 9.05 0.71 7.41 – 10.88 8.04 0.64 6.36 – 10.00 169.59 0.36 *** MLMC4 61.56 4.39 50.46 – 75.21 56.75 3.37 49.45 – 64.91 113.25 0.28 *** WHMC4 14.25 1.25 12.06 – 19.24 12.63 1.02 10.69 – 15.55 151.46 0.35 *** WBMC4 14.92 1.3 11.41 – 17.61 13.19 1.04 9.92 – 15.19 159.9 0.34 *** WMMC4 7.53 0.73 5.49 – 9.28 6.5 0.57 5.24 – 8.21 183.1 0.38 *** MLMC5 56.23 5.68 46.28 – 68.80 51.95 3.53 35.77 – 60.70 61.35 0.17 *** WHMC5 15.3 1.28 11.79 – 18.37 13.42 1.05 10.13 – 15.23 194.78 0.38 *** WBMC5 14.83 1.3 12.26 – 18.51 12.99 1.05 11.07 – 17.05 181.03 0.4 *** WMMC5 8.74 0.93 6.97 – 11.20 7.45 0.73 5.71 – 9.45 179.56 0.38 *** MLPP1 34.38 2.31 29.53 – 39.86 31.55 2.14 26.80 – 37.24 120.85 0.29 ***
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Measurement a Male (n = 150) Female (n=150) F R-‐square p-‐value
Mean SD Range Mean SD Range WHPP1 15.41 1.23 8.56 – 15.73 13.66 0.97 7.19 – 13.84 186.55 0.3 *** WBPP1 12.27 1.25 11.90 – 19.09 10.79 0.99 10.01 – 15.62 129.26 0.38 *** WMPP1 8.27 0.91 5.98 – 10.75 7.15 0.81 4.98 – 8.92 128.01 0.3 *** MLPP2 43.3 2.47 37.42 – 49.53 40.52 2.49 34.64 – 47.65 93.84 0.24 *** WHPP2 17.89 1.02 9.68 – 15.44 15.8 0.87 9.62 – 13.05 363.88 0.39 *** WBPP2 12.46 0.94 15.41 – 20.96 11.15 0.68 13.70 – 18.01 191.18 0.55 *** WMPP2 10.37 0.78 7.95 – 12.42 9.08 0.68 7.27 – 11.11 233.75 0.44 *** MLPP3 48.24 2.99 40.68 – 56.09 44.85 2.61 38.96 – 52.13 109.6 0.27 *** WHPP3 17.55 1.11 10.67 – 16.10 15.4 0.86 10.22 – 13.62 353.43 0.41 *** WBPP3 13.23 0.97 15.15 – 20.16 11.78 0.75 13.34 – 17.85 210.08 0.54 *** WMPP3 10.61 0.86 8.56 – 12.57 9.1 0.73 7.11 – 10.71 268.07 0.33 *** MLPP4 45.36 2.85 37.91 – 52.40 41.68 2.44 35.68 – 48.19 158.22 0.33 *** WHPP4 16.23 1.08 10.19 – 15.37 14.32 0.93 9.35 – 12.88 268.68 0.42 *** WBPP4 12.35 0.88 13.87 – 19.58 10.98 0.72 12.19 – 16.43 214.88 0.47 *** WMPP4 9.94 0.86 7.58 – 12.22 8.36 0.72 6.21 – 10.13 297.82 0.5 *** MLPP5 36.05 2.16 29.04 – 42.20 32.82 2.16 27.89 – 39.77 158.22 0.35 *** WHPP5 15.31 0.99 8.15 – 12.70 13.45 0.82 7.54 – 11.52 314.58 0.29 *** WBPP5 10.38 0.84 13.27 – 18.88 9.35 0.75 11.50 – 16.13 124.17 0.51 *** WMPP5 8.53 0.84 6.41 – 11.07 7.16 0.74 5.16 – 8.97 223.08 0.43 ***
Key: a Definition of measurements in Table 5.1; NS = not significant; *P<0.05, **P<0.01, ***P<0.001
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5.3.4 Discriminant function analyses
Discriminant function analyses were performed using different measurement
combinations. As it is possible that a complete hand may not always be available
for assessment in a forensic or archaeological context, demarking points were
calculated for each individual hand bone measurement; only the most accurate
function for each bone is reported. Thereafter, a series of direct multiple variable
and stepwise discriminant analyses were performed using measurements acquired
from the metacarpals alone, as these bones are more likely to be recovered in a
forensic or archaeological context.
i) Direct single variable functions
Demarking points were calculated for each of the 40 measurements acquired in
the hand to assess whether sex could be accurately estimated using a single
measurement. The combined cross-‐validated accuracy for the most accurate
variable for each bone is reported in Table 5.5, and ranged from 76.70 (Function 4;
WMMC4) to 85.70% (Function 7; WBPP2). Function 10 (requiring the base width
of proximal phalanx five WBPP5) is considered to be the most accurate variable for
estimating sex, as it had both a combined cross-‐validated accuracy above 80%
(85.30%) and a sex bias below 5% (-‐4.00%). Of the ten most accurate functions,
eight involve base width measurements.
ii) Direct multiple variable functions
A series of direct multiple variable discriminant analyses were performed for the
combined metacarpal measurements. There were only two metacarpals that
yielded accuracy above 80%; metacarpals two and five (Table 5.6). Functions 11
and 12 have classification accuracies of 84.00% and 84.30% respectively.
However, Function 11 should be used in preference to Function 12, as it has a
considerably smaller sex bias (-‐4.00% compared to -‐8.70%).
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Table 5.5 Direct single variable discriminant analyses of individual hand bones, including demarking point values (in mm).
Measurement# Demarking
points
Combined cross-‐
validated accuracy Sex bias
Metacarpal
Function 1. WBMC1 ♀ <15.98< ♂ 81.70% -‐ 2.00%
Function 2. WBMC2 ♀ <19.82< ♂ 81.30% -‐ 4.00%
Function 3. WHMC3 ♀ <16.22< ♂ 81.30% -‐ 6.70%
Function 4. WMMC4 ♀ < 7.02< ♂ 76.70% -‐ 6.70%
Function 5. WBMC5 ♀ <14.36< ♂ 80.30% -‐ 7.30%
Proximal Phalanx
Function 6. WBPP1 ♀ <14.53< ♂ 78.30% -‐ 0.70%
Function 7. WBPP2 ♀ <16.84< ♂ 85.70% -‐ 6.00%
Function 8. WBPP3 ♀ <16.48< ♂ 87.00% -‐ 7.40%
Function 9. WBPP4 ♀ <15.27< ♂ 81.30% -‐ 4.00%
Function 10. WBPP5 ♀ <14.38< ♂ 85.30% -‐ 4.00%
Key: #Definition of measurements in Table 5.1; ♂ = Male, ♀ = Female
Table 5.6 Direct multiple variable discriminant analysis of metacarpals.
#Equation: unstandardised coefficients and constant
Group centroids &
sectioning point
Correctly assigned
Sex bias
Function 11. Metacarpal Two
(0.41 x MLMC2) + (0.315 x WBMC2) + (0.181 x
WHMC2) + (0.567 x WMMC2) -‐17.108
♂ 1.024 ♂ 123/150; -‐ 4.00% 0.00 ♀ 129/150
♀ 1.024 [84.0%]
Function 12. Metacarpal Five
(0.037 x MLMC5) + (0.375 x WBMC5) + (0.244 x
WHMC5) + (0.525 x WMMC5) 15.005
♂ 0.994 ♂ 120/150; -‐ 8.70% 0.00 ♀ 133/150
♀ 0.994 [84.3%]
Key: #Definition of measurements in Table 5.1; ♂ = Male, ♀ = Female
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iii) Stepwise discriminant analysis
A stepwise discriminant function analysis was performed, for the complete hand
(Function 13) and for each individual digit (Functions 14 to 18) (Table 5.7). The
stepwise discriminant function analysis of the complete hand selected eight
variables and achieved a cross-‐validated classification accuracy of 91.00% with a
sex bias of -‐6.00%. The stepwise discriminant function analysis of measurements
from each of the five digits resulted in classification accuracies from 79.70 to
87.70%. The highest sex classification accuracy was achieved for the fifth digit
using six variables (see Function 18; Table 5.7) with a cross-‐validated accuracy of
87.70% and a sex bias of -‐2.00% (Table 5.7).
5.3.5 Posterior probabilities
Posterior probability intervals for the 18 functions are provided in Appendix One
(Table A1.1). The overall percentage of individuals classified with a certainty of
above 80% for each of the direct discriminant functions (1-‐12) was less than that
calculated for the stepwise functions (13-‐18). Function 13 had the highest
percentage of correctly classified individuals within the ‘0.80-‐1.00’ interval for
both males (91.73%) and females (89.44%). The lowest percentage of individuals
classified with 80% and above certainty for males (54.17%) was calculated for
Function 1 and for females it was Function 3 (54.33%). There were no individuals
correctly classified in any discriminant function with less than 40% certainty.
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Table 5.7 Stepwise discriminant function analysis of the Western Australian adult sample.
Step #Variables Unstandardised coefficient
Standardised coefficient
Wilk’s lambda
Structure point
Group centroids
Sectioning point
Correctly assigned
Sex bias
Complete Hand
Function 13.
1 2 3 4 5 6 7 8
WBPP2 WMPP4 MLPP5 WHPP5 WBPP1 MLPP2 WBPP3 MLMC1 Constant
0.325 0.610 0.257 -‐0.590 0.190 -‐0.199 0.327 0.090 -‐18.107
0.308 0.486 0.572 -‐0.470 0.210 -‐0.495 0.325 0.275
0.450 0.411 0.395 0.378 0.369 0.360 0.352 0.346
0.803 0.727 0.530 0.469 0.575 0.408 0.792 0.509
♂ 1.371 ♀ -‐1.371
0.00 91.00% -‐6.00%
Individual Digits
Function 14.
1 2 3
WBMC1 MLMC1 WBPP1 Constant
0.400 0.112 0.336 -‐16.51
0.507 0.342 0.371
0.589 0.544 0.522
0.873 0.732 0.828
♂ 0.953 ♀ -‐0.953
0.00 79.70% -‐8.70%
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Step #Variables Unstandardised coefficient
Standardised coefficient
Wilk’s lambda
Structure point
Group centroids
Sectioning point
Correctly assigned
Sex bias
Function 15.
1 2
WBPP2 WMMC2 Constant
0.866 0.379 -‐17.94
0.823 0.289
0.450 0.434
0.968 0.703
♂ 1.137 ♀ -‐1.137
0.00 86.70% -‐8.00%
Function 16.
1 2 3
WBPP3 WMPP3 MLMC3 Constant
0.576 0.530 0.058 -‐18.56
0.573 0.423 0.233
0.457 0.429 0.418
0.923 0.804 0.561
♂ 1.175 ♀ -1.175
0.00 86.00% -‐5.40%
Function 17.
1 2 3
WMPP4 MLPP4 WBPP4 Constant
0.759 0.141 0.306 -‐17.74
0.604 0.373 0.310
0.500 0.441 0.427
0.864 0.601 0.820
♂ 1.154 ♀ -‐1.154
0.00 85.70% -‐6.00%
Function 18.
1 2 3 4
WBPP5 WMMC5 WBMC5 WMPP5
0.580 0.295 0.226 0.391
0.527 0.246 0.265 0.309
0.486 0.454 0.446 0.437
0.872 0.659 0.686 0.734
♂ 1.175 ♀ -‐1.175
0.00 87.70% -‐2.00%
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Step #Variables Unstandardised coefficient
Standardised coefficient
Wilk’s lambda
Structure point
Group centroids
Sectioning point
Correctly assigned
Sex bias
5 6
WHPP5 MLPP5 Constant
-‐0.425 0.113 -‐16.75
-‐0.338 0.251
0.429 0.419
0.548 0.618
Key: #Definition of measurements in Table 5.1; ♂ = Male, ♀ = Female
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5.4 Population differences
5.4.1 Measurement differences
To evaluate the significance of metrical population variation the mean adult
metacarpal length measurements were compared to previously published data
from a selection of populations foreign to Australia (Table 5.8); the results are
outlined in Appendix Two (Table A2.1). Metacarpal length was the one
measurement common to the five comparative studies and was therefore
compared using a series of unpaired t-‐tests. The t-‐values reported for each of the
significance tests is an indication of the size of the difference between the two
means that were compared. A high positive t-‐value suggests that Western
Australian mean metacarpal length values are statistically significantly different
than their foreign counterparts.
Metacarpal length measurements were statistically significantly different for all
comparisons between Western Australian males and females and the comparative
populations, with the exception of the maximum length of metacarpal one between
Western Australian and Egyptian populations. The largest t-‐values, and thus
largest differences, were reported for the comparison of male mean metacarpal
one and two lengths between the Western Australian and the British populations
(t = 7.46 and t = 8.62 respectively). The largest t-‐value (t = 6.70) was found when
comparing the male mean for metacarpal four maximum lengths between Western
Australian and American populations. The lowest t-‐values, and therefore smallest
differences, were calculated when comparing Western Australian males to
Egyptian males for all three mean metacarpal length measurements.
A different trend was found when comparing the Western Australian female data
to the four comparative populations. Western Australian female mean values were
significantly larger than the Spanish population for metacarpal one (t = 5.34), two
(t = 10.14) and four (t = 7.01). Metacarpal one length values between the Western
Australian and Egyptian were not significant (t=0.09); corresponding p-‐value
indicating that these mean values were not statistically significantly different. In
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considering the lengths of metacarpal two and four, the Western Australian
females were most similar to the British population.
Table 5.8 Four comparative populations (including source of data and sample size)
#Caucasian or African American not stipulated
5.4.2 Variation in the expression of sexual dimorphism
The significance of sex differences in mean metacarpal within the Western
Australian and comparative populations were also evaluated using a series of
independent sample t-‐test. The results are presented in Appendix Three (Table
A3.1) and offer an indication of the magnitude of sexual dimorphism expressed by
the maximum length of metacarpals one, two and four for each five population.
All comparisons were found to be statistically significantly different for metacarpal
one; the largest difference was found when comparing male and female mean
values within the American population (t = 10.36; p <0.05). However, the largest
sex in metacarpal two and four was found in the Egyptian population (t = 11.96, p
<0.05 and t = 13.61, p <0.05 respectively). Overall, the British population had the
lowest level of sexual dimorphism in the three metacarpal lengths compared
(Appendix Three, Table A3.1). It is also evident that the magnitude of sexual
dimorphism expressed in the hand bones of Western Australian individuals was
most similar to the level of sexual dimorphism expressed in the British population
as demonstrated by the similar t-‐values reported.
Publication Population Males Females
Scheuer and Elkington (1993) Caucasian-‐British 33 27
Barrio et al. (2006) Spanish ancestry 36 36
Case and Ross (2007) Caucasian American and European
133 116
El Morsi and Hawary (2012) Egyptian Ancestry 100 100
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5.4.3 Classification accuracy
To further explore the need for population specific sex estimation standards,
discriminant functions for populations foreign to Western Australia were used to
classify individuals in the present study. The function that had measurements in
common with the current study, and the highest stated classification accuracy,
were used to classify the Western Australian sample. It was found that the
achieved classification accuracy is considerably lower than classification
accuracies originally reported (Table 5.9). The discriminant functions applied to
the current sample, excluding the North American discriminant function of Case
and Ross (2007), had a tendency to misclassify males as females. Conversely, the
Case and Ross (2007) function misclassified more than half the female sample as
male; overall the application of all the foreign functions resulted in extremely large
sex-‐bias values (Table 5.9).
Table 5.9 Classification accuracies when applying foreign standards to a Western Australian population
Reference Published Accuracy
Achieved Accuracy on the current population Sex Bias
Male Female Pooled
Scheuer and Elkington 1993
80.00% 5.33% [8/150] 100% [150/150] 52.66% -‐94.77%
Barrio et al. 2006
91.40% 0.00% [0/150] 100% [150/150] 50.00% -‐100%
Case and Ross 2007
83.10% 96.00% [144/150] 47.33% [71/150] 71.67% 48.67%
El Morsi and Hawary 2012
83.90% 2.67% [4/150] 68.00% [102/150] 35.34% -‐65.33%
The function that achieved the highest classification accuracy (71.67%) when
applied to the Western Australian population was that of Case and Ross (North
American) (2007). This function also achieved the smallest sex bias value of
48.67%. However, this considerably large sex bias renders the function
inapplicable to a Western Australian population, as female individuals are likely to
be misclassified as males. The largest sex bias value (-‐100%) was found when
using the Spanish function of Barrio et al. (2006). The lowest overall classification
accuracy was 35.34% when the Egyptian function of El Morsi and Hawary (2012)
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65
standard was applied. Overall, it is clearly evident that all four foreign standards
are completely unacceptable for application in a Western Australian population.
5.5 Sub-‐adult analyses
Another aim of the present study was to assess the age at which sex can be
accurately estimated in the sub-‐adult hand. A series of ANOVA’s were performed to
assess the significance of metric dimorphism at different ages: Group A (12-‐14
years); Group B (14-‐16 years); Group C (16-‐18 years). This was then followed by a
series of discriminant function analyses to quantify sex classification accuracy with
these age groups. The effect of classifying the sub-‐adults in each age group using an
adult discriminant function was also evaluated.
5.5.1 Age distribution
As discussed in Chapter Four, the sub-‐adult sample was split into three groups to
quantify the age at which the hand bones are significantly sexually dimorphic. The
mean, range and standard deviation for each of the three age groups is outlined in
Table 5.10.
Table 5.10 Distribution of age (in years) for each of the sex-‐specific sub-‐adult groups.
Age group Sex n Range Mean Standard Deviation
Group A Male 10 13.10 – 13.80 13.52 0.30
(12 – 14 years) Female 11 12.70 – 13.80 13.46 0.35
Group B Male 20 14.10 – 15.60 14.92 0.51
(14 – 16 years) Female 20 14.20 – 15.70 15.08 0.49
Group C Male 20 16.10 -‐17.90 17.09 0.59
(16 – 18 years) Female 19 16.10 – 17.60 16.87 0.49
5.5.2 Measurement normality
Normality was tested using the Shapiro-‐Wilk method. In the male sample 39 out of
40 measurements were normally distributed. The base width of proximal phalanx
five was the only measurement that was not normally distributed. A total of five
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66
measurements in the female sample were found to violate assumptions of
normality; the base width of metacarpal two, proximal phalanx two and proximal
phalanx three, and the head width of proximal phalanx two and four. These
measurements were not removed as further analyses of these measurements were
considered to be relatively robust to violations of normality (as discussed above).
5.5.3 Univariate comparisons
The descriptive statistics for the sub-‐adult hand bone measurements are presented
in Appendix Four. In Group ‘A’, the males have (in general) smaller mean
measurement values than the females of the same age group. It is evident that from
approximately 14 years of age, however, males have larger mean measurement
values than females. The results from the ANOVA comparisons show a tendency
for F-‐statistic values to increase as the age of the sample group increases
(Appendix Four). The majority of mean differences between males and females in
Group ‘A’ were found to be insignificant and more measurements start to become
statistically significantly different between males and females in Group ‘B’. All
comparisons in Group ‘C’ were found to be statistically significantly different.
5.6 Sex classification accuracy in the sub-‐adult hand
i) Discriminant function analysis
Stepwise discriminant function analysis was conducted for each of the three sub-‐
adult age groups (Table 5.11). The function produced for group ‘B’ had the highest
cross-‐validated accuracy of 95.00% using five measurements; however, the sex
bias was 10.00%. Group ‘A’ had the lowest cross-‐validated accuracy of 76.20% and
an associated sex bias of 8.30%. Group ‘C’ had a cross-‐validated classification
accuracy of 92.30%, but also had the largest sex bias value of the three groups
(-‐15.00%).
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67
Table 5.11 Stepwise discriminant functions based on the analysis of the sub-‐adult sample
Groups Step #Variables Unstandardised coefficient
Standardised coefficient
Wilk’s lambda
Structure point
Group centroids
Sectioning point
Correctly assigned
Sex bias
Function 19.
(Group A)
1
WMPP4 Constant
1.332 -‐10.738
1.000 0.655
1.000
♂ 0.723 ♀ -‐0.658
0.0325 76.20% 8.30%
Function 20.
(Group B)
1 2 3 4 5
WBMC1 WMMC4 WHPP4 WBMC4 WMPP3 Constant
0.587 1.210 -‐1.221 0.720 0.922 -‐20.614
0.516 0.791 -‐1.213 0.671 0.762
0.482 0.381 0.325 0.263 0.216
0.545 0.471 0.200 0.322 0.490
♂ 1.857 ♀-‐1.857
0.00
95.00%
-‐10.00%
Function 21.
(Group C)
1 2 3
WHPP2 WBMC2 WMMC1 Constant
0.917 0.405 0.583 -‐23.560
0.599 0.490 0.453
0.318 0.285 0.280
0.724 0.687 0.507
♂ 1.706 ♀-‐1.795
-‐0.0445
92.30%
-‐15.00%
Key: #Definition of measurements in Table 5.1; ♂ = Male, ♀ = Female
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68
ii) Classifying sub-‐adults using an adult classification model
To explore the effect of applying an adult discriminant function to sub-‐adults, the
adult stepwise discriminant function (Table 5.7, Function 13) was used to classify
the sub-‐adults in each age group. For all three groups, the female individuals were
all correctly classified and for the males the highest classification accuracy
achieved was 65.00% for Group ‘C’. Group ‘C’ also had the smallest sex bias (-‐
35.00%), whilst group ‘A’ had the largest sex bias (-‐70.00%). Clearly, however, all
of the sex bias values render this function not forensically applicable to the sub-‐
adult population.
Table 5.12 Sex classification accuracies of adult Function 13 to the sub-‐adult sample
Group Number of males correctly classified
Number of females correctly classified
Sex bias
A 3/10 (30.00%) 10/10 (100.00%) -‐70.00% B 9/20 (45.00%) 20/20 (100.00%) -‐55.00% C 13/20 (65.00%) 19/19 (100.00%) -‐35.00%
5.7 Interaction effects
Regression analysis was performed to test for interaction effects between sex and
age to evaluate whether age has any effect on strength of the relationship between
hand size and sex. No statistically significant interactions were found between age
and sex for group ‘A’, ‘B’ or ‘C’. This suggests that any statistically significant
differences found between sub-‐adult males and females are independent of age.
69
CHAPTER SIX
Discussion and conclusions
6.1 Introduction
The purpose of the present study was to quantify the magnitude of hand bone
sexual dimorphism and to concurrently establish sex estimation standards for a
Western Australian population. The latter is important because sex estimation is
more accurate when the standards applied are population specific. A precision test
was conducted prior to data collection to establish the most reliable method for
acquiring linear data from hand x-‐rays. Thereafter, the ‘line-‐tool’ method was used
to acquire adult and sub-‐adult measurements that were statistically analysed to
quantify the level of morphometric dimorphism. Discriminant function analysis
was then performed to quantify the accuracy of sex estimation; the results of those
analyses are discussed, in addition to considering forensic applications, limitations
and future research directions. A final conclusion is then presented.
6.2 Measurement precision
The first aim of the present study was to assess which method of acquiring
measurements in digital x-‐rays was the most accurate, reliable and practical for
data acquisition. A precision test (technical error of measurement, relative
technical error of measurement and coefficient of reliability) was performed using
the landmark and line-‐tool acquisition methods. This was important because
unacceptably high measurement error can affect the validity of the study;
specifically the robustness of the subsequent statistical analyses and prediction
models.
All hand bone measurements acquired using both methods produced ‘acceptable’
rates of measurement error (See Table 5.1 and 5.2). The rTEM is a standardised
version of TEM and measurements are considered imprecise if this statistic is
above 5% (Goto & Mascie-‐Taylor 2007; Ulijaszek & Kerr 1999). The R value
provides an estimation of how much variation is not attributable to measurement
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70
error and thus R values closer to 1 are indicative of precise measurement
acquisition. Overall, the line-‐tool method had a lower average rTEM (1.33%) than
the landmark method (1.77%) and more measurements with an R value equal to 1
(20 compared to 12 for the landmark method). The slight difference in these
statistics between the line-‐tool and landmark methods are likely related to
differences in the measurement system affecting repeatability. For example, the
landmark method required the location of extremal landmarks in each hand bone,
which are known as “Type III landmarks” (Bookstein 1991, pp.65; O’Higgins 2000).
The 3D (x, y, z) co-‐ordinates of the landmarks were then used to calculated the
inter-‐landmark distances, without knowing whether the placement of those
landmarks would result in a true maximum linear distance. The line-‐tool method,
however, involves drawing a line between two landmarks, which enables a direct
measurement. Once the line was drawn, each end of the line could be moved
medio-‐laterally or in a proximal/distal direction in order to find a true maximum
linear distance. The latter resulted in greater consistency between the repeated
measurements, as verified by the precision test results (Table 5.2).
The rTEM and R values in the present study are consistent with previous research;
R values > 0.9 and rTEM values < 5% for linear measurement acquisition (e.g.
Arroyo et al. 2010; Franklin et al. 2012b; Ulijaszek and Kerr 1999; Ishak et al.
2012). The precision test confirms that accurate measurements can be taken in
digital hand x-‐rays, as previously suggested by Verhoff et al. (2008) and Franklin et
al. (2012c), who both examined measurement precision in actual bone specimens
and multi-‐slice computer tomography scans. Verhoff et al. (2008) assessed the
variance between measurements acquired from actual skull specimens and their
three dimensional (MSCT) reconstructions. The physical and digital measurements
varied on average by 1-‐3mm. Franklin et al. (2012c) reported an even smaller
difference when comparing traditional cranial measurements acquired in physical
bone specimens and their MSCT counterparts (digitised in OsiriX®); the mean
difference was only 0.9mm and statistically non-‐significant between the two
acquisition methods.
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6.3 Adult data
6.3.1 Sexual dimorphism in the hand
As the overall purpose of this study was to produce population-‐specific sex
estimation standards, the magnitude and expression of sexual dimorphism in the
hand bones was first quantified. The ability to accurately estimate sex in the
human skeleton is inherently related to sex-‐specific morphological and
behavioural differences (Glücksmann 1981; Frayer & Wolpoff 1985). The degree to
which sexual dimorphism is expressed, and the age at which males and females
begin to vary morphologically, is dependent on genetic and environmental factors
that differ between populations. For this reason, therefore, it is recommended that
sex estimation standards are population specific, which affords the most accurate
possible sex classification (Burrows et al. 2003; Franklin et al. 2012b; Franklin et
al. 2013).
i) Hand bone measurements
In the present study mean male measurements were significantly larger than their
female counterparts (See Table 5.4). In general, the base width, head width and
mid-‐shaft width measurements were more dimorphic (greater ‘between-‐sex’
variance) compared to the maximum length measurements. The latter is congruent
with previous research in British (Scheuer and Elkington 1993), Spanish (Barrio et
al. 2006) and Greek (Manolis et al. 2009) populations. Scheuer and Elkington
(1993) reported their highest index of separation (the difference between the male
and female mean divided by the pooled standard deviation) for the mediolateral
base width of metacarpal two, whilst Barrio et al. (2006) reported that this same
measurement resulted in the highest sex classification accuracy (91.00%). Manolis
et al. (2009) also suggest that epiphyseal widths are the most accurate indicators
of sex, as they generally exhibit morphometric sexual dimorphism to a greater
extent than length measurements. Previous studies examining the fleshed hand
also suggest that width and breadth measurements are more sexually dimorphic
than length measurements. (e.g. Ishak et al. 2012, Alboul-‐Hagag et al. 2011).
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72
The observation that hand width measurements (both skeletal and fleshed)
express a greater degree of sexual dimorphism could be related to functional
loading in response to mechanical stimulus (e.g., Moss 1980; Trinkaus et al. 1994;
DiBennardo & Taylor 1979; Carter et al. 1996). Functional loading (put simply) is
the transformation in size, shape or mass reflected in the distribution of cortical
bone that skeletal tissue can potentially undergo in response to mechanical loading
or “…patterns of habitual biomechanical stress” (Trinkaus et al. 1994, pp.2; see also
Moss 1980).
Trinkaus et al. (1994) and Wilczak (1998) suggest that longitudinal measurements
(such as maximum length) are less likely to be affected by any physical stresses
resulting from habitual activity. Trinkaus et al. (1994), in particular, compared the
humeral diaphyseal and articular dimensions in six different groups; a
Neanderthal sample and five recent human groups from different populations (one
of which consisted entirely of professional tennis players). Trinkaus et al. (1994)
concluded that variance in diaphyseal measurements were heavily influenced by
mechanical loading, as evidenced by the high level of bilateral asymmetry
exhibited by the professional tennis players (maximum of 57% difference in
diaphyseal dimensions), as compared to the four ‘recent’ human samples
(maximum of 14% difference). Maximum bone length and articular dimensions
were found to exhibit minimal levels of asymmetry across all six samples.
Wilczak (1998) reported similar results when comparing mean muscle insertion
areas, as well as length and articular dimensions, of African-‐American, Euro-‐
American and four American Indian populations. Not only did diaphyseal (muscle
insertion) areas differ between individuals of a different ancestral background
(African-‐American, Euro-‐American and American Indian), they also differed within
the four Native American groups. They suggest that this was likely due to different
subsistence methods, and concluded that diaphyseal breadths are more sensitive
to mechanical stresses (after skeletal maturation) than are length and articular
dimensions (Wilczak 1998).
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73
ii) Sex estimation potential
Sex is often the first component of the biological profile estimated because the
remaining elements (age, stature and ancestry) are generally estimated using sex-‐
specific methods (Franklin 2012a, Braz 2009). It is important, therefore, to use the
most accurate sex estimation standards, because misclassification may have a flow
on effect that reduces the accuracy of the estimation of other biological attributes.
A series of single variable discriminant analyses were performed to derive a
classification function for each metacarpal and phalanx analysed (See Table 5.5);
combined cross-‐validated accuracies ranged from 76.70% (mid-‐shaft width of
metacarpal four) to 87.00% (base width of proximal phalanx three). The
classification potential of using all four measurements from a single metacarpal
was also considered; however, only two of the resulting functions had cross-‐
validated accuracies over 80% (See Table 5.6). A series of stepwise discriminant
function analyses based on measurements from the complete hand, and from each
individual digit, were also performed (See Table 5.7). The stepwise analysis of all
hand bone measurements resulted in the highest cross-‐validated accuracy
(91.00%; sex bias -‐6.00%) based on the analysis of eight variables.
As discussed previously (see above) the width measurements were more sexually
dimorphic than the maximum length measurements. This was further confirmed
by examining the functions that had accuracy rates above 85%; there were more
width measurements included in these functions, which also had higher
standardised coefficient values than the length measurements (if length
measurements were included at all). However, functions with classification
accuracies over 85% are not necessarily reliable if they misclassify either males or
females at disproportionate levels. For this reason, the sex bias was calculated and
functions with a bias greater than ± 5% (such as Function 8; classification accuracy
of 87.00% and sex bias of -‐7.40%) should thus be applied with caution, despite a
high degree of expected cross-‐validated accuracy.
In the present study, the lowest cross-‐validated classification accuracy (76.70%)
was for Function 4 based on the measurement of the mid-‐shaft width of
metacarpal four (See Table 5.5). The highest cross-‐validated classification accuracy
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74
(91.00%) was for Function 13, requiring a total of eight hand measurements in the
hand (See Table 5.7). Generally, the functions that included multiple
measurements achieved a higher accuracy; this observation is also consistent with
previous research (e.g. Scheuer & Elkington 1993; Barrio et al. 2006; Case & Ross
2007).
There are a number of studies that have examined the sex estimation potential of
hand bones within different ethnic groups, including: Caucasian British (Scheuer
and Elkington 1993); Caucasian and African American (Burrows et al. 2003; Case
and Ross 2007); Spanish (Barrio et al. 2006); and Egyptian (El Morsi and Hawary
2012) populations. The results of the latter studies are summarised in Table 6.1.
The range of sex classification accuracy in the present study (76.70 -‐ 91.00%) is
well within that of the published literature. When comparing the results of the
present study to the global populations in Table 6.1, the classification accuracy
range for the Egyptian population (66.80 -‐ 83.90%) is clearly the most different.
However, the results of the latter study are obviously different compared to all of
the global populations listed. This is likely due to the lack of stepwise discriminant
functions in the Egyptian study or the exclusion of width measurements. As
already discussed, width measurements were found to be the most dimorphic
variables ; and as they were not considered in the Egyptian study, this may be why
classification accuracies were not as high as that of the current study. From Table
6.1 it is evident that the classification accuracy ranges achieved for the current
study were most similar to those of Scheuer and Elkington (1993). This similarity
could be due to the common ethnic origin of both populations, which is supported
by 2011 census statistics for Western Australia, where 79% of that population are
self-‐reported to be of English ancestry (ABS 2012).
The current study achieved the third highest classification accuracy (91.00%) of
the five studies listed in Table 6.1. However, the two studies that reported higher
classification accuracies were based on considerably smaller samples (n<72), as
opposed to the present study (n = 300). In considering a larger sample size, the
results from the current study are more statistically robust, as they are based on a
broader cross-‐section of the local population. The discriminant functions produced
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75
are, therefore, more likely to perform with comparable accuracy when applied to
the broader Western Australian population.
Table 6.1 Sex classification accuracy of adult hand bone measurements in a variety of global populations.
Publication Population Sample size (n) Classification accuracy range
Current study Western Australian ♂ =150 ♀ = 150 76.70 -‐ 91.00%
Scheuer and Elkington 1993
Caucasian-‐British ♂ =33 ♀ = 27 74.00 -‐ 94.00%
Barrio et al. 2006
Spanish ♂ =36 ♀ = 36 81.20 -‐ 91.40%
Case and Ross 2007 Caucasian-‐American and European
♂ =133 ♀ = 116 77.90 -‐ 84.30%
El Morsi and Hawary 2012
Egyptian ♂ = 100 ♀ = 100 66.80 – 83.90%
In the present study posterior probabilities were calculated for all 18 functions
(see Appendix One); these are used as a statistical indication of confidence in
classifications. Higher posterior probability values are indicative of a discriminant
score that is well above (or below) the sectioning point (Patriquin et al. 2005). The
function that produced the highest classification accuracy (Function 13) had the
highest percentage of individuals classified at 80% certainty and above (90.59%),
thus suggesting it is unlikely those individuals were classified by chance. No
individuals within the sample were classified at lower than 40% certainty. This
provides some degree of statistical confidence that functions derived from the
Western Australian sample should be applicable to the broader population in a
forensic context. Functions 1 to 6 had the lowest percentages of individuals
(ranging from 55.80 to 64.82%) classified at 80% certainty or above. This would
suggest that the functions based on a sole metacarpal variable are not as robust as
the direct multiple variable and stepwise discriminant functions.
In considering the accuracy of skeletal sex assessments in general, the pelvis and
cranium are the preferred bones used to estimate that particular biological
attribute (Franklin et al. 2014). The pelvis, in particular, is considered the most
dimorphic bone as it has a specific morphology related to biological function (e.g.
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76
accommodating childbirth in females). For the pelvis alone, sex classification
accuracy rates have been reported between 90 to 95% (Phenice 1969; Lovell
1989; Ubelaker & Volk 2002). High classification accuracies have also been
reported for the skull, ranging from 75 to 90% (e.g. Giles & Elliot 1963; Franklin et
al. 2005) and the long bones: between 83 to 96% for the humerus (Spradley &
Jantz 2011; Robinson & Bidmos 2008; Albanese et al. 2005); 85 to 94% for the
radius (Spradley & Jantz 2011); 76 to 97% for the femur (Albanese et al. 2008;
Robinson & Bidmos 2011; Spradley & Jantz 2011); and 54 to 91% for the tibia
(Robinson & Bidmos 2011; Spradley & Jantz 2011). The range of classification
accuracies resulting from the standards presented in the present study are
comparable to those previously reported for other skeletal elements; further
confirming that hand bones from a Western Australian population are sexually
dimorphic and can be used to accurately estimate sex.
6.3.2 Morphometric population variation
A series of independent sample t-‐tests were conducted to investigate the
significance of population variation in hand bone measurements. It should be
noted that not all of the comparative studies acquired data from radiographs.
Comparisons are therefore made with caution. The maximum length
measurements of metacarpals one, two and four were compared, because they
were measurements common to the present study and the four comparative
studies. When comparing Western Australian male mean metacarpal length values
to the four comparative populations, all but one comparison was statistically
significantly larger (maximum length of metacarpal one for the Western Australian
and Egyptian individuals.). A similar trend was also examined when comparing
Western Australian females to the comparative populations; again, the only
statistically insignificant difference was found for metacarpal one to the Egyptian
population.
The relative magnitude of sexual dimorphism expressed in the hand bones was
also compared between populations; Western Australian population was most
similar to the British population. The purpose of these t-‐tests was to observe if
there was a difference in both mean metacarpal values and the magnitude of
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77
sexual dimorphism expressed between populations. Due to the degree of variation
between these populations (both morphometrically and in the relative magnitude
of sexual dimorphism expressed by the hand bones), life-‐time activity, prevalence
of malnutrition, climate and temporal (or secular) variation are all considered as
potential contributors to the variation assessed and are further discussed below.
i) Life-‐time activity
Life-‐time activity, both during and after skeletal maturation, can affect bone size
and shape (Wells 2007). Based on the analysis of the effect of improved nutrition
over time on the length and proportion of long bones, Jantz and Jantz (1999)
suggest that longitudinal bone dimensions (such as length) are less likely to be
affected by “patterns of habitual biomechanical stress” once skeletal maturation has
been reached. Both male and female long bone lengths were found to increase by
less than 1% per decade. Studies that have examined population variation in
skeletal robusticity (e.g. Collier 1989; Wilczak 1998) independently confirm this
trend, as both studies demonstrated population variation in diaphyseal and
epiphyseal, rather than length, measurements. For this reason, life-‐time activity
was dismissed as a factor affecting the morphometric variation in length
measurements between the populations examined in the present study.
ii) Malnutrition and quality of life
Malnutrition is a health issue concerned with the disproportionate consumption of
nutrients; either too much, not enough, in the wrong proportions, or affected by
malabsorption (World Health Organisation 2014). Malnutrition is measured by the
World Health Organisation (2013a) as the occurrence of height stunting;
calculated as the percentage of children under five years old who were more than
two standard deviations shorter than the expected height for their age. World
Health Organisation statistics (2013a), however, suggest that malnutrition in
children under five years of age in Australian and American populations is
minimal; metacarpal length differences between these populations is therefore,
most likely a result of factors other than inadequate nutrition. Data acquired from
an Australian sample in 2007 indicated that only 1.8% of children under the age of
five fell into this category. For America, the same statistic (as of 2002) is 3.9%
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78
(World Health Organisation 2013a). No such statistics were found for Spain and
the United Kingdom. However, as Western Europe (as for Australia and America)
is considered a developed region, it is unlikely that Spain and the United Kingdom
would have a significantly high prevalence of malnutrition. It is therefore also
unlikely that malnutrition is a causative factor for the existing morphometric
variation between the current study and the aforementioned comparative studies.
Egypt had the highest percentage of children with a height less than two standard
deviations expected for their age with the World Health Organisation (2013a;
2013c) reporting 30.7% of children under five exhibiting height stunting as of
2010. It is possible that malnutrition has been an influencing factor on metacarpal
length.
Along with malnutrition, the difference in ‘how developed’ the five populations are
was also considered. Comparative measures (such as the quality of life index and
the human development index) and statistics such as mortality rate, and life
expectancy at birth, are presented in Table 6.2.
Table 6.2 Quality of life statistics, quality of life index and human development
index for each of the five comparative populations.
Australia Egypt Spain United Kingdom
United States
Mortality rate# i, ii, iii, iv, v. 5 21 4 5 8
Life expectancy at birthvi 82 73 82 80 79
Quality of Life Indexvii Score 7.925 5.605 7.727 6.917 7.615 Rank 6 80 10 29 13
Human Development Indexviii
Score 0.938 0.662 0.885 0.875 0.937 Rank 2 112 23 26 3
Key: #. Mortality rate of children under five per 1000 live births; i. WHO 2013b; ii. WHO 2013c; iii.
WHO 2013d; iv. WHO 2013e; v. WHO 2013f; vi. OECD 2006; vii. The Economist 2005; viii. UNDP
2011.
The quality of life index is a score (out of 10) that is calculated using information
including (but not limited to) overall population well-‐being, health, family
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79
relations, job security, and political freedom (The Economist 2005). Out of 111
countries, Australia is ranked the highest of the five populations considered at
number six with a score of 7.925 (Table 6.2). Spain (number 10), America (number
13) and the United Kingdom (number 29) all rank in the top 30% of countries with
scores of 7.727, 7.615 and 6.917 respectively. Egypt, however, is within the bottom
30% (number 80) with a score of 5.605.
The human development index is another comparative measure based on factors
such as life expectancy, literacy skills, education, standards of living, and overall
quality of life. This index is on a scale from zero to one; values closer to zero are
indicative of an underdeveloped country and vice versa. Australia has the highest
human development index (0.938) and is placed at number two out of 186
countries (UNDP 2011). Egypt is, once again, the lowest ranked out of the five
countries considered (number 112), with the lowest human development index of
0.662, suggesting it is the least developed of the five populations. Quality of life is
also expressed through life expectancy and child mortality statistics. Egyptians
have a lower quality of life than Australian, Spanish, British and American
individuals. For instance, not only do Egyptians have a lower life expectancy at
birth (73 years old) than the four ‘more developed’ populations, the mortality rate
for children under five years is much higher (21 per 1000 live births) than any of
the other populations considered.
The statistics and indices outlined in Table 6.2 suggest that the quality of life in
Australia is similar to the quality of life in Spain, the United Kingdom and the
United States. It is, therefore, unlikely (as with the prevalence of malnutrition) that
difference in quality of life is a contributing factor to the morphometric differences
and differences in the expression of sexual dimorphism that exist between the
Western Australian population and the Spanish, British and American populations.
Whether prevalence of malnutrition and difference in quality of life are factors
relating to the unexpected similarities between the Western Australian and
Egyptian populations is uncertain. However, when considering the prevalence of
malnutrition and quality of life, it was expected that the Egyptian population
would exhibit the smallest magnitude of sexual dimorphism. Individuals of an
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80
Egyptian population are more likely to be subjected to poor nutrition, inadequate
access to water and lower quality of life than individuals from the more
‘developed’ comparative populations. It is therefore possible that individuals from
the Egyptian population study would not reach their full “genetic potential for
growth” (Mielke et al. 2011, pp.274) as a result of poor nutrition and quality of life.
Populations from countries that are considered to be less (or under) developed
have a tendency to express sexual dimorphism at a smaller magnitude than
populations from developed countries. This a reflection of males being more
susceptible to growth stunting factors (such as poor nutrition) than females
(Harrison et al. 1977) resulting in males and females being morphometrically
similar and less sexually dimorphic. This, however, was not what the results of the
t-‐test depicted.
iii) Climate
Another factor that can affect levels of morphometric variation, or the degree of
sexual dimorphism expressed by the hand bones in different populations, is
climate. With regards to biological and morphological variation, Allen (1877) and
Bergmann (1847; cited in Collier 1989) proposed rules concerning body
composition in relation to climate. Bergmann’s rule suggests that individuals with
a larger body-‐weight in proportion to their overall body size are more suited to
cooler climates, and individuals with a smaller body weight in proportion to their
overall body size, are more suited to a warmer climate. This negative correlation
between body-‐weight and mean temperature was confirmed by Roberts (1953);
the mean body-‐weight of populations from Africa, South-‐East Asia and Australia
were significantly lower than the mean body-‐weight of American and European
populations. As the present interpretation is focussing on population variation in
metacarpal length, Allen’s rule is more relevant to this comparison than
Bergmann’s rule.
Allen’s rule concerns the length of extremities in relation to climate; individuals
subject to cooler climates are expected to have shorter limbs, along with a lower
surface area to allow for sufficient heat retention (Allen 1877). In warmer climates,
the opposite is expected; longer extremities coupled with a larger surface area
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81
(relative to body size) to decrease heat retention (Allen 1877; Collier 1989). It is,
therefore, expected that taller individuals would have longer limb bones and by
association (resulting from a scaling effect) longer hand bones. Both Western
Australia and Spain are considered to have Mediterranean climates, and it was
therefore expected that the mean metacarpal length values may be similar (Bureau
of Meteorology 2014). As the Egyptian population are subject to a more arid
climate, reaching higher maximum temperatures than Western Australia, Egyptian
mean metacarpal length values were expected to be larger than their Western
Australian counterparts (Egyptian Meteorological Authority 2014; AEMET 2014).
The results of the present study, however, do not reflect the latter relationship.
The results (Appendix Two) suggest that Western Australian metacarpal lengths
for both males and females are significantly larger than those of Spanish
individuals. The metacarpal lengths of Western Australian individuals were
actually found to be most similar to the Egyptian individuals, despite the
expectation that the Western Australian population would be significantly smaller.
As with the previous factors discussed, climate alone cannot explain the
differences and similarities (and dissimilarities) found when comparing the
Western Australian and comparative populations. Whether climate actually has, or
the extent climate does have, an effect on hand bone size is uncertain. In a
historical context, this relationship between climate and body shape and size
would have been more likely. However, in a modern context, humans can
effectively adapt their environments to suit them; thus minimising the effect
climate has on body type and size (i.e. Allen’s and Bergmann’s rules).
iv) Secular variation
In examining the comparative populations it is evident that the Caucasian-‐British
(Scheuer & Elkington 1993), Spanish (Barrio et al. 2006) and Caucasian-‐American
(Case & Ross 2007) are temporally removed to the contemporary Western
Australian sample (Table 6.3). This temporal difference may be the reason for the
size difference examined; secular changes in height as well as long bone size and
proportion are all well documented (e.g. Tanner 1962; Van Wieringen 1986; Jantz
& Jantz 1999; Bielecki et al. 2012). Secular changes in height have been established
CHAPTER SIX
82
as a positive linear trend with an average 1-‐1.5cm increase in mean height every
decade, regardless of population (Tanner 1962; Van Wieringen 1986). In Polish
school-‐aged boys an increase of up to 3.43cm in mean height was found when
compared data from the previous decade (Bielecki et al. 2012). Ljung et al. (1974)
also found a secular change in mean height in Swedish children (measured
between 1965 and 1971) who had a larger mean height (an average increase of
2.5cm every decade) than Swedish children measured in 1938. Similar results
were found when comparing data on stature and weight acquired from Melbourne
school students (5 to 17 years of age) with data acquired from up to 100 years
prior; from 1970 to 1992, a 1.2 centimetre increase per decade was for found for
male height at age 17 and a 0.2 centimetre increase per decade was found for
females height at age 17 in the Victorian (Australian) population (Loesch et al.
2000).
Table 6.3 Year of birth and year of death ranges of the three temporally different comparative studies.
Publication Sample Year of birth
range Year of
death range
Current Study Digital hand x-‐rays from various hospitals in Western Australia
1948 – 1995 NA
Scheuer and Elkington 1993
Cadavers from various medical schools in United Kingdom
1844 – 1930 1926 -‐ 1988
Barrio et al. 2006 Skeletal collection from Complutense University of Madrid
Unknown 1975 – 1985
Case and Ross 2007 Terry anatomical collection 1840 – 1950 1920 -‐ 1965
Key: NA = Not Applicable
With gradual secular generational increases in mean height values, it is likely that
changes have concurrently occurred in mean metacarpal length values. For
example, Jantz and Jantz (1999) found that the secular increase in long bone length
for both lower and upper limb bones had a similar gradual increase as height when
comparing generations. This may explain the more significant differences, between
mean metacarpal lengths from the current study and Scheuer and Elkington
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83
(1993), Barrio et al. (2006) and Case and Ross (2007) (See Appendix Two). Due to
a temporal variation between the latter three studies and the contemporary data
examined in the present study, differences in mean metacarpal lengths could be
the result of secular variation. With improved nutrition, sanitation, accessible
medical facilities and reduced incidence of childhood or infectious diseases,
contemporary populations have a tendency to exhibit larger bone dimensions than
previous generations by reaching their full “genetic growth potential”(Mielke et al.
2011, pp.274; Eveleth & Tanner 1976; Malina 1979).
v) Summary
The results from the independent sample t-‐tests confirm morphometric variation
in the hand bones. Furthermore, t-‐test results also confirm population differences
in the magnitude of sexual dimorphism. Differences in life-‐time activity, the
prevalence of malnutrition, climatic and temporal variation were all considered.
However, morphometric differences and variation in the magnitude of sexual
dimorphism is likely the result of multiple and largely unpredictable factors.
Without knowing which factors have had an effect on each of the populations, and
how much these factors have contributed to the expression of sexual dimorphism,
sex estimation standards based on morphometric hand bone data cannot be
accurately applied to foreign populations. This further emphasises the need for
population specific standards (see below).
6.3.3 Importance of population specific standards
Non-‐population specific standards may result in inaccurate results because
populations are known to differ in the expression and magnitude of sexual
dimorphism (Frayer & Wolpoff 1985). This issue has been investigated previously;
for example, Burrows et al. (2003) tested the applicability of previously
established sex estimation standards based on populations foreign to their
American sample. Sex-‐estimation standards for Caucasian-‐British (Scheuer and
Elkington 1993), mixed Caucasian-‐European and Caucasian-‐American (Case and
Ross 2007) and Caucasian-‐American and African-‐American were evaluated
(Stojanowski 1999). Sex estimation accuracy using the foreign models were up to
9.00% lower and the range of achieved accuracies was wider (e.g. Burrows
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84
reported an accuracy range of 65.2 to 95.7% when the original reported accuracy
range was 75 to 90%), indicating less consistency than originally reported.
However, the foreign estimation standards were tested on a relative small sample
(n=23), which had an age at death range of 64-‐93 years.
In the present study there was a tendency (similar to that demonstrated by
Burrows et al. 2003) for classification accuracies to be lower than initially reported
when foreign standards were applied to the Western Australian population. The
most accurate foreign standards (when applied to Western Australia) were those
of a North-‐American Caucasian population (Case and Ross 2007) however, due to
its extremely high sex-‐bias (48.67%), it would be completely unacceptable to use
this standard to estimate sex in Western Australian individuals.
6.4 Sub-‐adult sample
i) Sexual dimorphism
Another aim of the present study was to assess whether sex can be accurately
estimated in sub-‐adults and to determine at what age the hand bones are
quantifiably dimorphic. The results from the univariate comparisons suggest that
the hand bones are sexually dimorphic at approximately 14 to 16 years of age
(Group B; 14-‐16 years). The number of statistically significant sex differences
increased with increasing age. This likely related to the age of pubertal onset in
both males and females and the difference that exists in both pubertal and skeletal
growth between males and females (Gasser et al. 2013).
Franklin et al. (2007) examined the sex estimation potential of the mandible in
sub-‐adults from three separate populations, with results also suggesting that
males and females become morphologically dimorphic around the age of 15 years.
Although in that study multivariate regression analyses indicated that there were
no statistically significant differences between sub-‐adult males and females, it was
suggested that sex estimation could be possible at the age of 15 years, as p-‐values
for this age group were approaching significance. Franklin et al. (2007) proposed
that statistically significant differences may have been found had a larger sample
been considered.
CHAPTER SIX
85
Gasser et al. (2013) documented the appearance of several stages of pubertal
growth and the pubertal growth spurt in 120 boys and 112 girls from a Swiss
population. Females within this study were found to begin their pubertal growth
spurt approximately one year earlier than males, with their peak growth velocity
occurring between 12 to 12.5 years of age. The onset of the pubertal growth spurt
for the males in that study was between 10.75 and 11 years, with their peak
growth velocity occurring between 13.5 and 14 years of age. In considering the
results of the present study, the latter may explain the few statistically significant
differences between the male and female mean values in Group ‘A’ (12 to 14 years)
as opposed to Groups ‘B’ (14 to 16 years) and ‘C’ (16 to 18 years). Data acquired
from this same Swiss sub-‐adult sample was assessed for the onset, peak growth
velocity and maximal deceleration of skeletal growth, resulting in similar ages to
the stages of pubertal growth (Molinari et al. 2013). Peak skeletal growth occurred
at approximately 12.2 years in females and 14 years in males, which once again is
reflected in the increase of statistically significant differences between the sexes as
age increases.
ii) Sex classification accuracy
Stepwise discriminant functions were formulated for the three sub-‐adult age
groups. Group ‘B’ and ‘C’ had classification rates above 90%, which would suggest
that from 14 years of age sex can be accurately estimated. Despite achieving cross-‐
validated accuracies over 80% for Groups ‘B’ and ‘C’, their associated sex bias
values were greater than ± 5%, suggesting that these functions should be used
with due caution. When considering the sex bias values (-‐35 to -‐70%) sex
estimation of sub-‐adults is deemed to be unreliable and inaccurate. This may be
due to variation in the onset of pubertal growth and skeletal maturation, and the
ages associated with these two stages of development (see above). It is possible
that sex bias values would decrease if a larger sample for each age group was
considered, as a larger sample would include a broader cross-‐section of the sub-‐
adult population and therefore more variation.
Additionally, the adult sexing standard (Function 13) was also applied to the sub-‐
adult sample to establish whether the former is applicable to the non-‐skeletally
CHAPTER SIX
86
mature hand. It was clear the function based on the adult data is not suitable for
the application to sub-‐adults. For all three groups, the total number of females was
correctly classified (100% correctly classified). However, across the three groups,
the highest number of males correctly classified using the adult discriminant
function was 65.00%. This tendency for males to be misclassified as females may
be due to their later pubertal growth spurt and therefore, their later completion of
skeletal growth (Molinari et al. 2013). At the final stages of the pubertal growth
spurt, females were found to have reached 97% of their total adult height at the
age of 13.5 years, and males were found to have reached 96% of their total adult
height at 15.5 years. As the age limit of the individuals included in the sub-‐adult
sample was 17.90 years, it is possible that some of the male sub-‐adults classified
using the adult function were still growing and, therefore, were classified as female
due to their smaller hand dimensions.
In light of this possibility, Group C was scrutinised for skeletal maturity; all 20
females were observed to be skeletally mature (complete epiphyseal fusion) and
18 of the 20 males were skeletally mature. However, both male individuals with
incomplete fusion were correctly classified by the adult Function 13, negating the
suggestion that skeletal maturity is responsible for the sex bias observed. It is
beyond the scope of this research study to evaluate the reasons for the high degree
of male misclassification in skeletally mature sub-‐adults, although it is inevitably
related to small sample size, in collaboration with factors such as ancestry.
6.5 Forensic applications
The classification models produced in this study are designed for forensic
application when assessing sex from digital hand radiographs in Western
Australia. The functions presented are suited to varying levels of bone
preservation. In an ideal situation, data would be acquired from the complete
hand in order to classify sex using the stepwise model (Function 13) as it had the
highest classification accuracy and a reasonable sex bias value. However, the
likelihood of recovering a complete skeletal hand when a human body has already
progressed to the skeletal stage of decomposition is relatively lower compared to
other larger and more robust skeletal elements. Waldron (1987) calculated
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87
percentage recovery rates for different archaeological skeletal elements and found
a relatively strong correlation between the survival of skeletal elements and their
size. The phalanges were among the least well-‐represented skeletal elements,
likely due to their smaller size. Metacarpals were considered to be ‘fairly’ resistant
to post-‐mortem damage with recovery rates ranging from 39.80% for the right
fifth metacarpal to 63.60% for the left third metacarpal. Forensic cases are likely to
exhibit percentage recovery rates similar to those found by Waldron (1987) or
perhaps even worse depending on the manner of death (e.g. post-‐blast remains).
For this reason, sex estimation standards were formulated based on a single hand
bone; as these models do not require a complete hand, they can be applied in
situations where the hand bones have been disarticulated, fractured or in cases of
co-‐mingled amputated limbs, such as what may occur in disaster victim
identification (DVI) situations (Blau & Briggs 2011).
6.6 Limitations and future research
The current study examined both adult and sub-‐adult Western Australian
individuals. The large adult sample (n=300) afforded a robust analysis of the data
acquired, as potential sampling error would have been minimised. The number of
sub-‐adults from each of the three age groups examined, however, was
comparatively small (approximately 20-‐40). Further research into the sex
estimation potential of the sub-‐adult hand, based on the analysis of a larger
sample, would be beneficial. Research into bilateral asymmetry could also be
performed to assess the applicability of classification models from this study
(based on right hand measurements) to the left hand. Ishak et al. (2012) confirmed
that bilateral asymmetry had minimal effect on measurements from the fleshed
hand in a Western Australian population. This is also likely to occur for the hand
bones, but it is yet to be statistically quantified.
Another consideration for future research would be to conduct a longitudinal
study on morphometric differences in long bones, specifically including the
metacarpals and phalanges, to assess the magnitude of secular differences in
Western Australian individuals across generations. This may give an indication of
how reliable the classification models produced would be to past and future
CHAPTER SIX
88
generations, and perhaps necessitate the formulation of updated contemporary
classification models in the future.
Finally, it would be of interest to acquire data from an adult sample of known
ancestry. From the 2011 census, the Australian Bureau of Statistics reported that
over 25% of the Western Australian population were born overseas, whilst 20% of
the remaining population had at least one parent born overseas (Australian
Bureau of Statistics 2013). It would be to ascertain if accuracy varies between the
different ethnic groups in the Western Australian population (e.g. Asian and
European ancestry). Furthermore, the standards produced from this study should
be used to classify individuals from different states within Australia to establish if
these standards can be applied to the Australian population as a whole, as opposed
to just solely individuals from Western Australia.
6.7 Conclusions
Sex is generally the first component of the biological profile estimated; it is
required to be highly accurate and reliable, as remaining biological profile
components (age, stature and ancestry) are often based on sex-‐specific standards.
The results of the present study clearly demonstrates that precise and accurate
linear measurements can be acquired from digital hand x-‐rays. Measurement
precision values (rTEM and R) for both acquisition methods tested (landmark and
line-‐tool method) were high and comparable to measurement precision results
from previously published sex estimation studies (e.g. Ishak et al. 2012; Franklin et
al. 2012b).
The present thesis has also demonstrated that the hand bones are sexually
dimorphic in a Western Australian population and can be used to classify sex with
a high degree of expected accuracy. Cross-‐validated classification accuracies range
between 76.7 to 91% for the 18 functions presented; the highest classification
accuracy resulting from a combination of eight measurements in the complete
hand. Although the majority of the functions presented had cross-‐validated
classification accuracies above 80%, not all were forensically applicable; functions
with a sex bias value greater than ±5% should only be used with due caution, as
CHAPTER SIX
89
they have a tendency to misclassify either males or females at disproportionate
levels.
The final objective of this thesis was to determine the minimum age at which sex
can be reliably estimated in the hand bones. A series of ANOVAS were performed
to determine the age at which hand bones were metrically sexually dimorphic.
Males were found to have larger hand bone measurements from approximately 14
to 15 years of age. However, sex could not accurately be estimated when applying
stepwise discriminant functions based on sub-‐adult (or adult) data, as sex bias
values were considerably high (ranging from 8.3 to 70%).
The present study has formulated population specific sexing standards based on
morphometric hand bone measurements for a Western Australian population;
such data did not previously exist. This represents a valuable addition to the
database of human identification protocols currently being developed as part of
on-‐going research projects at the Centre for Forensic Science at the University of
Western Australia. The standards presented here can be used to classify sex in
unknown remains in many different forensic and/or archaeological scenarios.
Importantly, these standards are based on data that is representative of the
contemporary Western Australian population and are thus the most appropriate
method of skeletal sex estimation using the hand bones.
90
91
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Appendix One
Table A1.1 Posterior probabilities calculated for the adult discriminant functions 1 to 18.
Posterior Probability intervals
Males
Females
n % n % Function 1 0.00-‐0.19
0 0
0 0
0.20-‐0.39 0 0 0 0 0.40-‐0.59 21 17.5 11 9.02 0.60-‐0.79
34 28.33
40 32.79
0.80-‐1.00 65 54.17
71 58.19 Function 2 0.00-‐0.19
0 0
0 0
0.20-‐0.39 0 0 0 0 0.40-‐0.59 13 11.02 10 8.26 0.60-‐0.79
32 27.11
29 23.97
0.80-‐1.00 73 61.87
82 67.77 Function 3 0.00-‐0.19
0 0
0 0
0.20-‐0.39 0 0 0 0 0.40-‐0.59 16 13.68 11 8.66 0.60-‐0.79
34 29.06
47 37.01
0.80-‐1.00 67 57.26
69 54.33 Function 4 0.00-‐0.19
0 0
0 0
0.20-‐0.39 0 0 0 0 0.40-‐0.59 9 8.18 16 13.33 0.60-‐0.79
29 26.36
33 27.5
0.80-‐1.00 72 65.46
71 60.17 Function 5 0.00-‐0.19
0 0
0 0
0.20-‐0.39 0 0 0 0 0.40-‐0.59 16 13.91 15 11.9 0.60-‐0.79
30 26.09
40 31.75
0.80-‐1.00 69 60
71 56.35
APPENDIX ONE
106
Posterior Probability intervals Males Females
n % n % Function 6 0.00-‐0.19
0 0
0 0
0.20-‐0.39 0 0
0 0
0.40-‐0.59 14 11.97
14 11.86
0.60-‐0.79 32 27.35
36 30.51
0.80-‐1.00 71 60.68 68 57.63 Function 7 0.00-‐0.19
0 0
0 0
0.20-‐0.39 0 0
0 0
0.40-‐0.59 5 4.03
6 4.51
0.60-‐0.79 22 17.74
18 13.53
0.80-‐1.00 97 78.23 109 81.96 Function 8 0.00-‐0.19
0 0
0 0
0.20-‐0.39 0 0
0 0
0.40-‐0.59 5 4
8 5.88
0.60-‐0.79 22 17.6
22 16.18
0.80-‐1.00 98 78.4 106 77.94 Function 9 0.00-‐0.19
0 0
0 0
0.20-‐0.39 0 0
0 0
0.40-‐0.59 12 10.08
8 6.4
0.60-‐0.79 21 17.65
25 20
0.80-‐1.00 86 72.27 92 73.6 Function 10 0.00-‐0.19
0 0
0 0
0.20-‐0.39 0 0
0 0
0.40-‐0.59 4 3.2
9 6.87
0.60-‐0.79 25 20
21 16.03
0.80-‐1.00 96 76.8 101 77.1 Function 11 0.00-‐0.19
0 0
0 0
0.20-‐0.39 0 0
0 0
0.40-‐0.59 11 8.87
4 3.08
0.60-‐0.79 19 15.32
24 18.46
0.80-‐1.00 94 75.81 102 78.46
APPENDIX ONE
107
Posterior Probability intervals Males Females
n % n % Function 12 0.00-‐0.19 0 0 0 0 0.20-‐0.39
0 0
0 0
0.40-‐0.59 9 7.5
10 7.52
0.60-‐0.79 25 20.83
27 20.3
0.80-‐1.00 86 71.67 96 72.18 Function 13
0.00-‐0.19 0 0 0 0 0.20-‐0.39 0 0 0 0 0.40-‐0.59
6 4.55
3 2.13
0.60-‐0.79 5 3.79
12 8.51
0.80-‐1.00 122 91.73 127 89.44 Function 14
0.00-‐0.19
0 0
0 0
0.20-‐0.39 0 0
0 0
0.40-‐0.59 9 7.96 10 7.94 0.60-‐0.79 22 19.47 20 15.87 0.80-‐1.00 82 72.57 96 76.19 Function 15
0.00-‐0.19
0 0
0 0
0.20-‐0.39 0 0
0 0
0.40-‐0.59 4 3.22
10 7.35
0.60-‐0.79 15 12.1 21 15.44 0.80-‐1.00 105 84.68 105 77.21 Function 16 0.00-‐0.19 0 0 0 0 0.20-‐0.39
0 0
0 0
0.40-‐0.59 5 4
6 4.51
0.60-‐0.79 20 16
16 12.03
0.80-‐1.00 100 80 111 83.46 Function 17
0.00-‐0.19 0 0 0 0 0.20-‐0.39 0 0 0 0 0.40-‐0.59
9 7.26
7 5.26
0.60-‐0.79 10 8.06
12 9.02
0.80-‐1.00 105 84.68 114 85.72
APPENDIX ONE
108
Posterior Probability intervals Males Females
n % n % Function 18 0.00-‐0.19 0 0 0 0 0.20-‐0.39
0 0
0 0
0.40-‐0.59 7 5.38
5 3.76
0.60-‐0.79 15 11.54
17 12.78
0.80-‐1.00 108 83.08 111 83.46
APPENDIX TWO
109
Appendix Two
Table A2.1 Unpaired t-‐test results for the comparison of metacarpal one, two and four lengths from the current study to four previously published studies.
Publication compared to current study
Measurementa Sex t Significance
(p) Scheuer & Elkington 1993
MLMC1 M 7.46 ***
F 4.68 ***
MLMC2 M 10.56 ***
F 7.16 ***
MLMC4 M 5.62 ***
F 2.44 **
Barrio et al. 2006 MLMC1 M 4.06 ***
F 5.34 ***
MLMC2 M 8.62 ***
F 10.14 ***
MLMC4 M 5.97 ***
F 7.01 ***
Case and Ross 2007 MLMC1 M 5.05 ***
F 5.28 ***
MLMC2 M 9.64 ***
F 8.73 ***
MLMC4 M 6.70 ***
F 5.59 ***
El Morsi & Hawary 2012 MLMC1 M 1.06 NS
F 0.09 NS
MLMC2 M 5.70 ***
F 7.50 ***
MLMC4 M 1.74 *
F 5.48 ***
Key: #Definition of measurements in Table 5.1; NS = not significant; * P<0.05, ** P<0.01, ***P<0.001
110
APPENDIX THREE
111
Appendix Three
Table A3.1 Unpaired t-‐test results for the comparison of males and females for each of the five comparative populations considered
Publication Measurementa t Significance (p) Current Study MLMC1 4.14 *** MLMC2 3.80 *** MLMC4 3.76 *** Scheuer and Elkington 1993
MLMC1 2.61 * MLMC2 3.19 **
MLMC4 1.96 ** Barrio et al. 2006 MLMC1 8.39 ***
MLMC2 7.97 ***
MLMC4 7.06 ***
Case and Ross 2007 MLMC1 10.36 ***
MLMC2 10.36 ***
MLMC4 9.71 ***
El Morsi and Hawary 2012
MLMC1 9.40 *** MLMC2 11.96 ***
MLMC4 13.61 ***
Key: #Definition of measurements in Table 5.1; NS = not significant; * P<0.05, ** P<0.01, ***P<0.001
112
APPENDIX FOUR
113
Appendix Four Table A4.1 Descriptive statistics of mean sub-‐adult hand bone measurements (in mm) for Group A.
a Measurement Male (n = 10) Female (n=11) F R square p-‐value
Group A Mean SD Range Mean SD Range
MLMC1 45.2 1.94 42.38 -‐ 48.15 44.01 3.29 38.76 -‐ 49.21 0.98 0.05 NS WHMC1 14.16 1.64 11.66-‐16.58 13.48 0.56 12.48-‐14.70 4.62 0.08 * WBMC1 14.61 1.8 12.18-‐16.99 13.38 0.61 12.28-‐14.28 1.68 0.20 NS WMMC1 9.55 1.19 6.81-‐11.24 8.54 0.44 7.67-‐9.20 6.96 0.27 * MLMC2 68.06 3.76 63.17 -‐ 75.61 68.57 4.14 62.80 -‐ 76.00 0.09 0.00 NS WHMC2 13.99 2.12 11.68-‐17.39 14.08 1.48 11.14-‐16.40 0.08 0.00 NS WBMC2 18.59 1.81 16.43-‐21.13 18.28 2.99 15.18-‐26.59 0.01 0.00 NS WMMC2 8.34 1.32 6.83-‐10.44 7.3 0.49 6.20-‐7.98 5.98 0.24 * MLMC3 65.08 3.69 63.17 -‐ 75.61 63.57 3.6 58.61 -‐ 70.75 0.91 0.05 NS WHMC3 14.95 1.72 12.64-‐17.45 13.87 1.46 11.21-‐15.98 2.84 0.11 NS WBMC3 14.21 1.76 11.49-‐16.75 13.21 0.83 11.93-‐14.67 2.44 0.13 NS WMMC3 8.19 1.03 6.92-‐9.97 7.21 0.6 5.79-‐8.08 7.25 0.28 *
APPENDIX FOUR
114
a Measurement Male (n = 10) Female (n=11) F R square p-‐value
Group A Mean SD Range Mean SD Range
MLMC4 57.15 3.21 52.36 -‐ 62.51 56.66 3.59 51.87 -‐ 65.21 0.11 0.01 NS WHMC4 12.64 1.68 9.93-‐15.16 11.36 0.9 9.40-‐12.60 1.02 0.20 NS WBMC4 12.54 1.52 10.92-‐14.93 11.99 0.93 10.22-‐13.68 4.83 0.05 * WMMC4 6.63 0.96 5.22-‐8.15 6.04 0.59 4.92-‐7.05 2.88 0.13 NS MLMC5 51.53 4.05 41.38-‐55.40 51.77 3.31 45.13-‐57.93 0.02 0.00 NS WHMC5 12.16 1.17 10.53-‐13.74 11.36 0.87 9.69-‐12.52 1.49 0.15 NS WBMC5 13.78 1.9 10.96-‐16.84 13.05 0.62 11.91-‐13.94 3.28 0.07 NS WMMC5 8.1 1.08 5.57-‐8.98 7.01 0.57 6.21-‐8.11 8.56 0.31 ** MLPP1 31.36 2.69 28.33-‐35.23 30.09 2.24 27.15-‐34.77 1.41 0.07 NS WHPP1 10.82 1.54 8.36-‐12.70 10.03 0.84 8.56-‐11.21 1.75 0.10 NS WBPP1 13.27 1.55 10.73-‐15.27 12.59 0.69 11.45-‐13.52 2.17 0.08 NS WMPP1 7.66 1.07 5.14-‐8.76 6.83 0.49 6.28-‐7.73 5.35 0.22 * MLPP2 40.05 1.98 36.89-‐42.49 39.83 2.31 36.35-‐43.02 0.05 0.00 NS WHPP2 10.68 1.05 8.96-‐11.82 10.46 0.41 10.04-‐11.53 2.26 0.02 NS WBPP2 15.28 1.31 13.71-‐17.94 13.98 0.57 13.09-‐15.14 0.42 0.11 NS WMPP2 9.1 1.02 7.54-‐10.73 8.17 0.6 7.34-‐9.25 6.6 0.26 * MLPP3 44.46 2.7 40.66-‐48.20 44.66 2.84 41.39-‐49.74 0.03 0.00 NS
APPENDIX FOUR
115
a Measurement Male (n = 10) Female (n=11) F R square p-‐value
Group A Mean SD Range Mean SD Range
WHPP3 11.3 1.44 8.99-‐13.18 11.29 0.58 10.67-‐12.46 9.63 0.00 ** WBPP3 15.32 1.3 13.45-‐17.92 13.98 0.57 13.09-‐15.14 0 0.34 NS WMPP3 9.33 0.94 7.91-‐10.78 8.34 0.64 7.26-‐9.29 8 0.30 * MLPP4 42.04 2.07 39.23-‐45.28 41.03 2.52 37.25-‐45.15 1.01 0.05 NS WHPP4 10.26 1.36 7.39-‐11.85 10.36 0.66 9.27-‐11.43 4.47 0.00 * WBPP4 13.74 1.09 12.00-‐15.95 12.93 0.62 11.51-‐13.48 0.04 0.19 NS WMPP4 8.61 0.87 6.92-‐9.98 7.57 0.62 6.74-‐8.38 9.99 0.34 ** MLPP5 32.84 1.95 29.74-‐35.50 32.19 1.82 30.31-‐35.35 0.63 0.03 NS WHPP5 8.92 1.18 6.74-‐10.29 8.35 0.26 7.88-‐8.65 1.67 0.11 NS WBPP5 13.03 1.2 10.84-‐14.43 12.52 0.51 11.34-‐13.13 2.46 0.08 NS WMPP5 7.1 0.92 5.40-‐8.67 6.41 0.78 5.42-‐7.65 3.42 0.15 NS
Key: #Definition of measurements in Table 5.1; NS = not significant; * P<0.05, ** P<0.01, ***P<0.001
APPENDIX FOUR
116
APPENDIX FOUR
117
Table A4.2 Descriptive statistics of mean sub-‐adult hand bone measurements (in mm) for Group B.
a Measurement Male (n = 20) Female (n=20) F R square p-‐value
Group B Mean SD Range Mean SD Range
MLMC1 47.53 3.11 42.72 -‐ 55.61 44.24 2.68 38.88 -‐ 50.16 12.83 0.25 *** WHMC1 15.11 1.59 12.41 -‐ 17.59 13.33 1.42 11.89 -‐ 17.12 40.89 0.12 *** WBMC1 14.74 1.01 13.72 -‐ 17.34 13.67 0.73 11.76 -‐ 14.64 5.04 0.52 * WMMC1 9.63 1.28 7.65 -‐ 12.34 8.69 0.87 7.20 -‐ 10.76 7.24 0.16 * MLMC2 70.52 4.69 61.41 -‐ 79.52 68.48 3.84 59.40 -‐ 74.89 2.27 0.06 NS WHMC2 19.29 1.74 12.38 -‐ 18.87 17.19 1.33 10.98 -‐ 15.73 24.66 0.16 *** WBMC2 15.42 1.61 16.09 -‐ 22.33 14.10 1.00 14.42 -‐ 18.78 7.19 0.39 * WMMC2 8.82 0.95 6.94 -‐ 10.48 7.71 0.71 6.70 -‐ 9.50 17.61 0.32 *** MLMC3 66.19 4.46 59.82 -‐ 74.08 63.64 3.76 55.68 -‐ 70.10 3.83 0.09 NS WHMC3 14.61 1.26 13.97 -‐ 18.67 13.34 1.30 11.83 -‐ 16.44 13.78 0.30 *** WBMC3 16.19 1.06 12.98 -‐ 16.57 14.55 1.09 11.61 -‐ 15.04 16.32 0.27 *** WMMC3 8.47 0.62 7.57 -‐ 9.63 7.59 0.62 6.72 -‐ 8.64 20.35 0.35 *** MLMC4 58.92 3.81 53.43 -‐ 65.69 56.22 3.31 49.74 -‐ 62.98 5.72 0.13 * WHMC4 13.00 0.98 11.74 -‐ 15.42 11.89 0.93 9.90 -‐ 13.46 14.28 0.39 *** WBMC4 13.56 1.07 11.82 -‐ 15.66 12.07 0.77 10.50 -‐ 13.46 24.19 0.27 ***
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a Measurement Male (n = 20) Female (n=20) F R square p-‐value
Group B Mean SD Range Mean SD Range
WMMC4 7.25 0.82 5.98 -‐ 8.87 6.10 0.43 5.35 -‐ 6.89 30.64 0.45 *** MLMC5 53.67 4.21 47.9 -‐ 62.93 51.47 2.88 45.6 -‐ 56.65 3.73 0.09 NS WHMC5 13.92 1.11 11.16 -‐ 14.89 12.84 1.01 8.54 -‐ 12.84 11.10 0.29 ** WBMC5 12.85 1.21 11.28 -‐ 16.06 11.54 0.81 11.17 -‐ 14.21 15.29 0.23 *** WMMC5 8.37 0.84 6.49 -‐ 9.92 7.08 0.75 5.91 -‐ 8.60 25.97 0.41 *** MLPP1 33.12 2.49 28.63 -‐ 37.55 30.48 1.70 27.18 -‐ 34.35 15.29 0.29 *** WHPP1 14.08 1.15 8.22 -‐ 12.98 12.80 1.02 8.26 -‐ 11.84 9.46 0.31 ** WBPP1 11.38 1.52 11.06 -‐ 16.2 9.96 1.09 10.99 -‐ 14.53 16.83 0.20 *** WMPP1 7.80 0.84 5.82 -‐ 9.2 6.92 0.69 5.43 -‐ 7.71 12.99 0.25 *** MLPP2 41.23 2.99 36.08 -‐ 46.55 39.89 2.52 34.86 -‐ 45.81 2.36 0.06 NS WHPP2 15.95 0.96 9.83 -‐ 13.19 14.74 0.81 8.38 -‐ 12.39 21.02 0.16 *** WBPP2 11.35 0.83 14.23 -‐ 17.3 10.58 0.84 12.31-‐ 16.03 7.46 0.36 ** WMPP2 9.58 0.93 7.3 -‐ 11.14 8.40 0.82 7.01 -‐ 11.05 17.98 0.32 *** MLPP3 46.50 3.06 41.61 -‐ 51.58 44.43 2.94 39.14 -‐ 50.93 4.77 0.11 * WHPP3 15.72 1.19 9.7 -‐ 14.79 14.39 0.72 9.53 -‐ 12.37 25.54 0.17 *** WBPP3 12.03 0.83 14.48 -‐ 17.43 11.17 0.83 11.86 -‐ 15.29 7.84 0.40 ** WMPP3 9.90 0.98 7.81 -‐ 11.8 8.40 0.64 7.24 -‐ 10.49 33.09 0.47 ***
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a Measurement Male (n = 20) Female (n=20) F R square p-‐value
Group B Mean SD Range Mean SD Range
MLPP4 43.12 3.05 38.05 -‐ 48.83 41.46 2.51 36.68 -‐ 48.39 3.52 0.08 NS WHPP4 14.33 1.17 9.32 -‐ 14.04 13.11 0.77 8.13 -‐ 11.94 20.69 0.13 ***
WBPP4 11.19 0.97 12.28 -‐ 16.31 10.45 0.72 11.29 -‐ 14.15 5.54 0.35 * WMPP4 9.05 1.07 6.9 -‐ 11.64 7.71 0.66 6.73 -‐ 9.85 22.52 0.37 *** MLPP5 33.80 2.96 27.96 -‐ 39.1 32.30 2.11 29.21 -‐ 37.63 3.41 0.08 NS WHPP5 13.46 0.87 7.2 -‐ 10.64 12.73 0.76 6.63 -‐ 10.02 8.20 0.15 ** WBPP5 9.12 0.94 11.07 -‐ 14.91 8.46 0.64 10.94 -‐ 13.73 6.60 0.18 * WMPP5 7.49 1.08 5.56 -‐ 9.46 6.29 0.60 5.15 -‐ 7.76 18.97 0.33 ***
Key: #Definition of measurements in Table 5.1; NS = not significant; * P<0.05, ** P<0.01, ***P<0.001
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Table A4.3 Descriptive statistics of mean sub-‐adult hand bone measurements (in mm) for Group C.
a Measurement Male (n = 20) Female (n=19) F R square p-‐value Group C Mean SD Range Mean SD Range
MLMC1 48.58 2.78 45.61 -‐ 54.18 45.14 2.47 40.34 -‐ 48.77 9.84 0.43 ** WHMC1 16.17 1.28 14.53 -‐ 19.1 13.64 0.96 11.68 -‐ 15.42 32.95 0.50 *** WBMC1 15.86 1.23 14.29 -‐ 18.46 13.92 0.79 12.6 -‐ 15.3 11.42 0.59 ** WMMC1 9.98 0.88 7.94 -‐ 11.3 8.49 0.65 7.65 -‐ 9.62 21.56 0.45 *** MLMC2 75.54 4.33 66.97 -‐ 81.48 68.44 3.61 61.47 -‐ 77.41 16.15 0.48 *** WHMC2 20.72 1.18 14.93 -‐ 18.93 17.40 0.84 12.85 -‐ 15.52 45.80 0.57 *** WBMC2 16.91 1.35 18.41 -‐ 23 14.24 1.04 15.04 -‐ 18.8 37.14 0.60 *** WMMC2 9.15 0.86 7.82 -‐ 11.14 7.93 0.57 6.93 -‐ 9.16 19.94 0.52 *** MLMC3 70.17 4.21 61.9 -‐ 79.21 63.73 3.69 56.25 -‐ 72.01 15.39 0.45 *** WHMC3 15.39 1.30 14.98 -‐ 20.14 13.74 1.09 13.04 -‐ 16.71 9.61 0.53 ** WBMC3 17.60 1.14 13.73 -‐ 18.79 15.00 0.73 12.67 -‐ 15.33 35.33 0.38 *** WMMC3 8.93 0.81 8.02 -‐ 11.08 7.88 0.63 7.06 -‐ 9.28 11.46 0.38 ** MLMC4 61.52 3.48 55.47 -‐ 68.32 55.91 3.34 48.18 -‐ 61.58 17.70 0.48 *** WHMC4 14.64 1.16 13 -‐ 17.24 12.26 1.06 10.58 -‐ 15.21 24.54 0.47 *** WBMC4 14.85 1.22 12.55 -‐ 17.52 12.80 0.64 11.28 -‐ 13.55 14.03 0.45 *** WMMC4 7.31 0.63 6.54 -‐ 8.35 6.68 0.73 5.38 -‐ 7.99 3.35 0.29 NS
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a Measurement Male (n = 20) Female (n=19) F R square p-‐value Group C Mean SD Range Mean SD Range
MLMC5 55.38 3.32 49.78 -‐ 61.31 52.01 2.43 47.39 -‐ 55.81 8.71 0.33 ** WHMC5 14.80 0.87 12.87 -‐ 16.14 13.19 0.74 11.52 -‐ 14.44 28.44 0.57 *** WBMC5 14.22 0.99 12.45 -‐ 16.3 12.52 0.74 11.77 -‐ 14.37 20.75 0.37 *** WMMC5 8.81 0.92 7.19 -‐ 10.58 7.42 0.57 6.19 -‐ 8.1 17.76 0.43 *** MLPP1 34.31 2.46 32 -‐ 39.69 31.55 1.75 27.29 -‐ 33.34 10.40 0.46 ** WHPP1 14.62 1.10 9.84 -‐ 13.87 12.50 0.79 8.32 -‐ 11.69 19.67 0.41 *** WBPP1 11.63 1.01 12.53 -‐ 16.7 10.06 1.03 10.06 -‐ 14.15 10.06 0.49 ** WMPP1 7.81 0.77 6.37 -‐ 9.4 6.62 0.77 5.34 -‐ 8.25 9.35 0.33 ** MLPP2 43.08 2.95 37.47 -‐ 48.03 40.03 1.63 35.95 -‐ 42.41 9.07 0.31 ** WHPP2 17.31 0.68 10.85 -‐ 13.33 15.10 0.62 9.29 -‐ 12.08 18.70 0.63 *** WBPP2 12.45 1.12 14.97 -‐ 20.3 10.52 0.92 13.49 -‐ 18.08 48.54 0.52 *** WMPP2 10.16 1.01 8.52 -‐ 11.91 8.60 0.64 7.35 -‐ 9.8 16.64 0.40 *** MLPP3 48.07 3.39 42.81 -‐ 54.16 44.77 2.09 40.86 -‐ 48.51 6.05 0.31 * WHPP3 16.98 0.81 10.93 -‐ 14.52 14.57 0.61 10.37 -‐ 12.9 21.06 0.61 *** WBPP3 13.19 1.28 13.97 -‐ 19.37 11.34 0.90 13.54 -‐ 17.55 28.99 0.48 *** WMPP3 10.26 0.99 8.39 -‐ 12.28 9.03 0.63 7.39 -‐ 9.83 12.31 0.34 ** MLPP4 45.55 3.64 39.54 -‐ 51.61 41.74 1.73 38.25 -‐ 44.22 8.56 0.36 **
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a Measurement Male (n = 20) Female (n=19) F R square p-‐value Group C Mean SD Range Mean SD Range
WHPP4 15.70 0.76 10.01 -‐ 13.28 13.58 0.65 9.87 -‐ 12.97 20.99 0.52 *** WBPP4 12.17 1.22 12.68 -‐ 18.58 10.64 0.63 12.8 -‐ 15.04 19.64 0.43 *** WMPP4 9.53 0.92 7.26 -‐ 10.49 8.10 0.59 7.11 -‐ 8.94 23.65 0.40 *** MLPP5 35.02 2.71 30.82 -‐ 41.46 32.78 1.50 29.37 -‐ 34.9 7.10 0.35 * WHPP5 14.61 0.74 8.66 -‐ 11.61 12.85 0.61 7.58 -‐ 10.23 43.66 0.50 *** WBPP5 10.20 0.76 12.3 -‐ 15.7 8.75 0.51 11.95 -‐ 14.15 25.67 0.60 *** WMPP5 7.71 0.96 5.73 -‐ 8.95 6.71 0.62 5.4 -‐ 7.85 8.21 0.30 *
Key: #Definition of measurements in Table 5.1; NS = not significant; * P<0.05, ** P<0.01, ***P<0.001
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