Smoothed Bootstrap Nelson-Siegel Revisited June 2010
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UNIVERSITEITANTWERPEN
EstimatingtheYieldCurveUsingtheNelsonSiegelModel
ARidge RegressionApproach
JanAnnaert
UniversiteitAntwerpen,Prinsstraat13,2000Antwerp,Belgium
AnoukG.P.Claes
LouvainSchoolofManagement,BoulevardduJardinBotanique43,1000Brussels,Belgium
MarcJ.K.DeCeuster
UniversiteitAntwerpen,Prinsstraat13,2000Antwerp,Belgium
HairuiZhang
UniversiteitAntwerpen,Prinsstraat13,2000Antwerp,Belgium
Abstract
TheNelsonSiegelmodeliswidelyusedinpracticeforfittingthetermstructureofinterestrates.Dueto
theease in linearizingthemodel,agridsearchoranOLSapproachusingafixedshapeparameterare
popularestimationprocedures.Theestimatedparameters,however,havebeenreported(1)tobehave
erraticallyovertime,and(2)tohaverelatively largevariances.WeshowthattheNelsonSiegelmodel
canbecomeheavilycollineardependingontheestimated/fixedshapeparameter.Asimpleprocedure
basedonridgeregressioncanremedythereportedproblemssignificantly.
Keywords:SmoothedBootstrap,RidgeRegression,NelsonSiegel,SpotRates
CorrespondingAuthorEmail:[email protected]
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1.Introduction
Goodestimatesofthe termstructureof interestrates (alsoknownasthespotratecurveorthezero
bond yield curve) are of the utmost importance to investors and policy makers. One of the term
structureestimationmethods, initiatedbyBlissandFama(1987), isthesmoothedbootstrap.Blissand
Fama(1987)bootstrapdiscretespotratesfrommarketdataandthenfitasmoothandcontinuouscurve
to thedata.Althoughvariouscurve fittingsplinemethodshavebeen introduced (quadraticandcubic
splines(McCulloch(1971,1975)),exponentialsplines(VasicekandFong(1982)),Bsplines(Shea(1984)
and Steeley (1991)), quartic maximum smoothness splines (Adams and Van Deventer (1994)) and
penalty functionbased splines (Fisher,Nychka and Zervos (1994),Waggoner (1997)), thesemethods
havebeencriticizedontheonehandforhavingundesirableeconomicpropertiesandontheotherhand
forbeing blackboxmodels (Seber andWild (2003)).Nelson and Siegel (1987) and Svensson (1994,
1996) therefore suggested parametric curves that are flexible enough to describe awhole family of
observed term structure shapes. Thesemodels are parsimonious, they are consistentwith a factor
interpretationofthetermstructure(LittermanandScheinkman(1991))andtheyhavebothbeenwidely
used inacademiaand inpractice. Inaddition to the level, slopeandcurvature factorspresent in the
NelsonSiegelmodel, theSvenssonmodel containsa secondhump/trough factorwhichallows foran
evenbroaderandmorecomplicatedrangeoftermstructureshapes.Inthispaper,werestrictourselves
totheNelsonSiegelmodel.TheSvenssonmodelsharesbydefinitionallthereportedproblemsof
theNelsonSiegel approach. Since the source of the problems, i.e. collinearity, is the same for both
models,thereportedestimationproblemsoftheSvenssonmodelmaybereducedanalogously.
TheNelsonSiegelmodel is extensively used by central banks andmonetary policymakers (Bank of
InternationalSettlements(2005),EuropeanCentralBank(2008)).Fixedincomeportfoliomanagersuse
themodel to immunize theirportfolios (Barrett,Gosnell andHeuson (1995) andHodges andParekh
(2006))andrecently,theNelsonSiegelmodelalsoregainedpopularityinacademicresearch.Dullmann
andUhrigHomburg(2000)usetheNelsonSiegelmodeltodescribetheyieldcurvesofDeutscheMark
denominated bonds to calculate the risk structure of interest rates. Fabozzi,Martellini and Priaulet
(2005)andDieboldand Li (2006)benchmarkedNelsonSiegel forecastsagainstothermodels in term
structureforecasts,andtheyfound itperformswell,especiallyfor longerforecasthorizons.Martellini
andMeyfredi (2007) use theNelsonSiegel approach to calibrate the yield curves and estimate the
valueatriskforfixedincomeportfolios.Finally,theNelsonSiegelmodelestimatesarealsousedasan
inputforaffinetermstructuremodels.Coroneo,NyholmandVidavaKoleva(2008)testtowhichdegree
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theNelsonSiegelmodelapproximatesanarbitragefreemodel.They firstestimate theNelsonSiegel
modelandthenusetheestimatestoconstruct interestratetermstructuresasan inputforarbitrage
freeaffinetermstructuremodels.TheyfindthattheparametersobtainedfromtheNelsonSiegelmodel
are not statistically different from those obtained from the pure noarbitrage affineterm structure
models.
Notwithstanding itseconomicappeal, theNelsonSiegelmodel ishighlynonlinearwhichcausesmany
users to reportestimationproblems.Nelson and Siegel (1987) transformed thenonlinearestimation
problem intoa simple linearproblem,by fixing the shapeparameter that causes thenonlinearity. In
ordertoobtainparameterestimates,theycomputedtheOLSestimatesofaseriesofmodelsconditional
uponagridofthefixedshapeparameter.Theestimatesthat,conditionaluponafixedshapeparameter,
maximizedtheRwerechosen.Werefertotheirprocedureasagridsearch.Othershavesuggestedto
estimate theNelsonSiegelparameterssimultaneouslyusingnonlinearoptimization techniques.Cairns
andPritchard(2001),however,showthattheestimatesoftheNelsonSiegelmodelareverysensitiveto
thestartingvaluesused in theoptimization.Moreover, timeseriesof theestimatedcoefficientshave
been documented to be very unstable (Barrett,Gosnell and Heuson (1995), Fabozzi,Martellini and
Priaulet(2005),DieboldandLi(2006),Gurkaynak,SackandWright(2006),dePooter(2007))andeven
to generate negative long term rates, thereby clearly violating any economic intuition. Finally, the
standarderrorsontheestimatedcoefficients,thoughseldomreported,arelarge.
Althoughtheseestimationproblemshavebeenrecognizedbefore,ithasneverleadtowardssatisfactory
solutions.Instead,itbecamecommonpracticetofixtheshapeparameteroverthewholetimeseriesof
termstructures.1Hurn,LindsayandPavlov (2005),however,pointout that theNelsonSiegelmodel is
verysensitivetothechoiceofthisshapeparameter.dePooter(2007)confirmsthisfindingandshows
thatwithdifferentfixedshapeparameters,theremainingparameterestimatescantakeextremevalues.
Hencefixingtheshapeparameterisanontrivialissue.Inthispaperweuseridgeregressiontoalleviate
theobservedproblemssubstantiallyandtoestimatetheshapeparameterfreely.
Theremainderofthispaperisorganizedasfollows.InSection2,weintroducetheNelsonSiegelmodel.
Section3presentstheestimationproceduresusedintheliterature,illustratesthemulticollinearityissue
which isconditionalontheestimated(orfixed)shapeparameterandproposesanadjustedprocedure
based on the ridge regression. In the subsequent section (Section 4)we present our data and their 1Barrettetal.(1995)andFabozzietal.(2005)fixthisshapeparameterto3forannualizedreturns.DieboldandLi(2006)chooseanannualizedfixedshapeparameterof1.37toensurestabilityofparameterestimation.
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descriptivestatistics.Sincetheridgeregressionintroducesabiasinordertoavoidmulticollinearity,we
willmainlyevaluatethemeritsofthemodelsbasedontheirabilitytoforecasttheshortandlongendof
thetermstructure.Theestimationresultsandtherobustnessofourridgeregressionarediscussed in
Section5.Finally,weconclude.
2.AfirstlookattheNelsonSiegelmodel
IntheirmodelNelsonandSiegel(1987)specifytheforwardratecurvef()asfollows:
( )( )
0 0 0/
1 1 1/
2 2 2
1,
/
ff e f
e f
= =
(2.1)
whereistimetomaturity,0,1,2andarecoefficients,with>0.
Thismodelconsistsofthreepartsreflectingthreefactors:aconstant(f0),anexponentialdecayfunction
(f1) and a Laguerre function (f2). The constant represents the (longterm) interest rate level. The
exponentialdecayfunctionreflectsthesecondfactor,adownward(1>0)orupward(10)ora trough (2
-
Figure1d
(respectiv
rate(thes
Fig
PanelA:F
Note:ThisfspotratecuPanelB)rep
Theroleo
time tom
vanishan
0.Based
tobeneg
compone
the slope
slope. Th
compone
depictstheth
velyr0,r1and
spotrate)cur
gure1:Decom
FortheForwa
figureshowstheurve(PanelB)wpresenttheleve
ofthecompo
maturity.Wh
dthelongte
oneconomic
gativeorunre
ntvanishesa
eof the term
e degree of
nt decay to
( )
= r
hreebuilding
r2inPanelB)
rve.
mpositionoft
ardRateCurv
edecomposedcwhentheshapepl,slopeandcurv
onentsbecom
en the time
rmforwarda
cintuition,w
ealisticallyhi
andtheforwa
m structure,w
the curvatu
o zero. Final
((
0
1
2
1
1 e
blocksofthe
)representth
theNelsonS
ve
componentsoftparameterisfixevaturecompone
mesclearwhe
tomaturity
andspotrate
weassume0
gh.Whenth
ardandthesp
whereby ane
re is control
lly, the loca
4
))
/
/
1
1 /
/
e
e e
eNelsonSieg
helevel,slope
iegelModelw
Pane
theNelsonSiegeedat3.Thecurentsoftheforwa
enwelookat
grows to inf
willconverge
tobecloset
etimetoma
potrateconv
egative (posit
led by 2, th
ation of the
=
0
1
/ 2
gelmodel.Th
eandcurvatu
withtheSha
elB:fortheS
elmodelforthervesf0,f1andf2ardrate(thespo
theirlimiting
finity, the slo
etothesame
otheempiric
aturityappro
vergeto(0+
tive) 1 repre
he rate at w
e maximum/
0
1
2
.rrr
hecurvesf0,f
urecompone
peParamete
SpotRateCur
eforwardratecinPanelA(respotrate)curve.
gbehaviourw
ope and curv
econstantlev
callongterm
oacheszero,o
1).Thespre
esents anup
which the slo
minimum va
f1andf2inPa
entsofthefor
erFixedat3
rve
urve(PanelA)apectivelyr0,r1an
withrespectt
vature compo
velofinterest
mspotratean
only thecurv
ead,1,mea
pward (downw
ope and curv
alue of curv
(2.3)
anelA
rward
andthendr2in
tothe
onent
trate,
ndnot
vature
asures
ward)
vature
vature
-
compone
the hump
functionw
structure.
In Figure
paramete
maximum
determine
PanelA:i
Note:This fvarious shawhereasthaEquation2.3
Alternativ
tomaturi
facilitates
themaxim
maximizin
hump/tro
ntisdetermi
p/trough of
with respect
.
2 the curvat
ers ranging fr
mwhen=,
edbysimply
intheForwar
figureshows thepeparameters.atinthespotra3withfixed.
vely,wecanf
ty,byfixingt
sestimation.
mumofthec
ng the curva
ough become
nedby.Not
the term str
to ,we ar
ture compon
rom 1 to 10
,whereas th
maximizingr2
Figure
rdRateCurve
eshapesof theThe curvature
atecurve(Panel
forcetheloca
theshapepa
Severalautho
curvaturecom
ature compo
es approxima
tethatdete
ructure. By m
e able to de
nent in the f
0. The curvat
at in thespo
2inEquation
e2:Shapesof
e
ecurvaturecomcomponent in tB)reachesitsm
ationoftheh
rametertoa
orsusethisid
mponentinth
onent in th
tely 1.37wit
5
erminesboth
maximizing th
etermine the
forward rate
ture compon
otratecurve
2.3withfix
ftheCurvatu
Pane
ponent in the fthe forward ratmaximumwhen
hump/trough
specificvalu
dea.Intheire
hespotratef
e spot rate
th annualized
theshapeof
he curvature
location of
and the spo
ent in the f
reaches itsm
xed.
ureCompone
elB:intheSp
forward rateante curve (Panel>,whichisd
oftheterm
ue.Thisalsol
empiricalwor
functionata
e function, t
d data. In Fa
fthecurvatu
e component
the hump/tr
ot rate are d
orward rate
maximumwh
nt
potRateCurv
d thespotrateA) reaches itsmdeterminedbys
structureto
inearizesthe
rk,Dieboldan
amaturityof
the shape p
abozzi et al. (
recomponen
t in the spot
rough of the
depicted for s
curve reach
hen >,wh
ve
curvewithrespmaximumwhensimplymaximizin
beatagiven
emodelandh
ndLi(2006)e
2.5years.Th
parameter o
(2005),wher
ntand
t rate
term
shape
es its
hich is
pect ton = ,ngr2in
ntime
hence
e.g.fix
husby
f the
re the
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6
shapeparameterwassettobe3,thehumpislocatedapproximatelyatamaturityof5.38onthespot
ratecurve.
3.Estimationprocedures
In order to obtain all the parameter estimates simultaneously, we could use nonlinear regression
techniques. Ferguson and Raymar (1998) and Cairns and Pritchard (2001), however, show that the
nonlinear estimators are extremely sensitive to the starting values used and that the probability of
gettinglocaloptimaishigh.Takingthesedrawbacksintoaccount,mostresearchershavefixedtheshape
parameterandhaveestimateda linearizedversionoftheNelsonSiegelmodel.Theparametersofthe
NelsonSiegelmodelhavetypicallybeenestimatedbyminimizingthesumofsquarederrors(SSE)using
(1)OLSoveragridofprespecifieds(NelsonandSiegel(1987)),and(2)alinearregression,conditional
onachosenfixedshapeparameter(DieboldandLi(2006),dePooter(2007),andFabozzietal.(2005)).
Werefertothesemethodsasthetraditionalmeasures.Theestimatedparametersusingthetraditional
methods, however, are reported (1) to behave erratically in time, and (2) to have relatively large
variances.We will first show that these problems result frommulticollinearity problems. Next, we
introducearidgeregressionapproachtoremedythereportedproblemsandhowtojudiciouslyfixthe
shapeparameterinordertoestimatethelinearizedNelsonSiegelmodel.
3.1.Thenatureofthemulticollinearityproblem
Researchershavebeen awareofpotentialmulticollinearity issueswhile estimating theNelsonSiegel
model.DieboldandLi(2006)e.g.indicatethatthehighcorrelationbetweenthefactorsoftheNelson
Siegel(1987)modelmakes itdifficulttoestimatetheparameterscorrectly.Whatseemstohavegone
unnoticed,however,isthefactthatthecorrelationbetweenthetworegressorsofthemodeldepends
on(thetimestomaturityof)thefinancialinstrumentschoseninthebootstrap.Inordertoillustratethis
point,weconsiderfourdifferentsetsoftimestomaturity:
1. 3and6months,1,2,3,4,5,7,10,15,20and30years;
2. 3,6,9,12,15,18,21,24,30months,310years;
3. 1week,112month,and210years;
4. 1week,6months,and110years.
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ThefirstsetofmaturitieswasusedbyFabozzietal.(2005).DieboldandLi(2006)optedforthesecond
maturity vector. Since researchersare inclined touseall thedata they can find,we study twoextra
vectorsthatalsoincludeadditionalshortertimetomaturities.
Table1summarizesthecorrelationsbetweentheregressorsforthevalueschosenbyDieboldandLi
(2006)andFabozzietal.(2005),usingthefourvectorsoftimetomaturitythatweconsider.Thetable
showsthatthecorrelationbetweentheslopeandthecurvaturecomponentoftheNelsonSiegelmodel
heavily depends on the choice of the shape parameter. The second maturity vector e.g. implies
correlationsvaryingbetween5%and87%dependingontheshapeparameterchosen.Thecorrelation
alsodependsseverelyonthechoiceofthetimetomaturityvector.Using=1.37,thecorrelationvaries
from0.549to0.256,forthematurityvectorschosen.Setting=3producescorrelationsfrom0.324to
0.931.Thevectorcontainingtheseriesofshortmaturities(thethirdvector)turnsouttobethemost
sensitivetothecollinearityissue.
Table1:CorrelationbetweenRegressorsUsingAlternativeTimetoMaturityVectors
MaturityVector DieboldandLi(=1.37) Fabozzietal.(=3)1 0.256 0.3242 0.051 0.8713 0.549 0.9314 0.352 0.872
Note:ThecorrelationsbetweentheregressorsintheNelsonSiegelspotratefunctionconditionedontheshapeparameterandthevectoroftimestomaturityarepresented.Vector1usesthefollowingtimestomaturity:3and6months,1,2,4,5,7,10,15,20and30years(asinFabozzietal.(2005));vector2uses3,6,9,12,15,18,21,24,30monthsand310years(asinDieboldandLi(2006));vector3isbasedon1week,112monthsand210years;andvector4on1week,6monthsand110years.
Figure3givesamorecompletepicturebyplottingthecorrelationbetweenthetworegressorsovera
rangeof valuesusing the four time tomaturity vectors studied.Wenotice that the choiceof the
maturityvector influencesthesteepnessofthecorrelationcurve. ItappearsthatFabozzietal.(2005)
andDieboldandLi(2006)chosetheirvaluesjudiciouslyconditionalontheirmaturityvector,although
they both motivate their choice differently. It is clear that for empirical work it is of the utmost
importanceforalloftheestimationmethodstotakethispotentialmulticollinearityissueintoaccount.
-
Note:Thisfratecurveo6months,1and310ye6monthsan
3.2Tradit
3.2.1Grid
Toavoidn
estimate
values ra
paramete
the time
(1995),Ca
anddePo
ofthisins
3.2.2OLS
Someres
curvature
Figur
figureplotstheovertheshapep1,2,4,5,7,10,ears(asinDiebond110years.
tionalestima
dsearchbase
nonlinearest
Equation2.3
nging from0
erset.Inprac
seriesofest
airnsetal.(2
ooter(2007).
stability.More
withfixedsh
earchersfixt
eofthespotr
re3:Correlat
correlationsbeparameterusin15,20and30yldandLi(2006)
tionmethod
edOLS
imationproc
3withordina
0.027 to1. T
ctice,itiswe
timates. This
001),Fabozzi
Farlessobse
eover,highm
hapeparame
theshapepa
rates.
tionsbetwee
tweentheslopengfourtimetomyears(asinFabo);vector3isbas
s
edures,Nelso
ry leastsqua
heestimates
llknownthat
hasbeenpo
ietal.(2005)
ervedisthat
multicollineari
eters
rameterwhic
8
ntheSlopea
eandcurvaturematurityvectorsozzietal.(2005)sedon1week,
onandSiegel
ares.Thispro
swith thehig
tgridsearch
ointedoutby
),Dieboldeta
multicollinea
itycanalsoin
chtheytypica
andCurvature
ecomponentofs.Vector1uses));vector2uses112monthsan
l(1987)linea
ocedurewas
ghestRwer
basedOLSle
ymany resea
al.(2006and
rityamongth
nflatethevari
allymotivate
eComponen
theNelsonSiegthefollowingtims3,6,9,12,15,nd210years;an
arizetheirmo
repeated for
re then chos
eadstoparam
archers inclu
d2008),Gurka
hetworegre
ianceofthee
ebypriorkno
t
gelmodelforthmestomaturity18,21,24,30mndvector4on1
odelbyfixing
rawholegrid
sen as theop
meterinstabi
dingBarrett
aynaketal.(
ssorsisthes
estimators.
owledgeabou
hespoty:3andmonths1week,
and
dof
ptimal
lityin
et al.
2006)
ource
utthe
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9
DieboldandLi (2006)set to16.4withmonthlycompounded returns,orapproximately1.37with annualized data. Their choice implies that the curvature component in the spot rate
functionwillhave itsmaximalvalueatthetimetomaturityof2.5years.Theymotivatedtheir
choicebystatingthatmostofthehumps/troughsarebetweenthesecondandthethirdyear.As
we have shown, this choice, also turned out to avoid multicollinearity problems for their
maturityvector.
Fabozzietal.(2005)fixedto3withannualizeddata,asarguedbyBarrettetal.(1995).Barrettetal. (1995)performedagrid searchby fixing for thewholedatasetandobtainedaglobal
optimalshapeparameterinonego.Inafootnote,Fabozzietal.(2005)mentionthatwhenthe
shapeparameterisfixedat3,thecorrelationbetweenthetworegressorswillnotcausesevere
problems for their data. They, however, do not offer a universal procedure to tackle the
multicollinearityissue.
Fromtheprevioussection,weknowthatthedegreeofmulticollinearitydependsonthechoiceofthe
fixed shapeparameterand the choiceof the vectorof times tomaturity.The shapeparameter that
minimizesthesquarederrorsmayalsovaryovertime.Figure4plotsthespotratecurveontwodays(i.e.
April18,2001andJanuary4,1999)wherefixingtheoptimalshapeparametertoeither1.37or3visually
underperformscomparedtothegridsearch.Thevaluesestimatedusingthegridsearcharereported
inthefigure.Onthelefthandside,theshapeparameterisestimatedtobe1.35.Theuseofafixedof
1.37willthereforeresultinabetterfitthanthemodelwithashapeparameterfixedat3.Ontheright
handside,however,thegridsearchestimateofis2.9.Themodelusingafixedof3willthusfitthe
databetterthanthatusingashapeparameterof1.37.
-
PanelA(
Note:Thisf(2.9)whichparametero
3.2.3Grid
Whereas
optimal e
Nelsonan
paramete
ridge reg
therefore
discussed
implemen
3.2.3.1M
In order t
collinearit
number.
TheVIFis
Fig
Date:April18
figuregivesaneminimizesthe fof1.37(3)result
dsearchwith
linear regres
estimators, th
ndSiegelsap
er.Conditiona
gression whe
need to tes
below. Su
ntationofthe
Measuringthe
to address th
tymeasures
definedas
ure4:AnExa
8,2001)
exampleofthelfittingerrors intsinabetterfit
conditional
ssionsdonot
heydo suffer
pproachbyco
alon the th
never the d
st the degre
bsequently,
eridgeregres
degreeofm
hemulticollin
include thev
ampleofthe
imitationoffixePanelA (Panelthanthemodel
ridgeregress
t require star
r from instab
ombiningthe
hat results in
egree of mu
ee of multico
we discuss
sionfortheN
ulticollineari
nearity issue,
variation infla
10
Limitationof
Pane
edshapeparameB).Asaconseqwithafixedsha
sion
rtingvalues f
bility inparam
egridsearch
n thehighest
ulticollinearit
ollinearity of
the nature
NelsonSiegel
ty
,we need to
ation factor (
fFixedShape
elB(Date:Ja
eter.Thegridsequence,theNelapedparameter
for theestim
meter estima
withtheOLS
R, thepara
ty among th
the two fac
e of ridge
termstructu
o verify the d
(VIF), the tole
eParameter
nuary4,199
earchgivesashsonSiegelmodof3(1.37).
matorsandal
ation. In this
Sregressiont
ametersare r
e regressors
ctors. The m
regression
ureestimation
degree of co
erance level
9)
apeparameterelwitha fixeds
waysgiveglo
paper,we f
tofreethes
reestimated
s is too high
measure we u
and present
n.
ollinearity. Po
and thecon
of1.35shaped
obally
follow
shape
using
h. We
use is
t the
opular
dition
-
11
21 ,
1 iR
whereRi isthecoefficientofmultipledeterminationofthe independentvariableXionallotherXs in
themodel.TheintuitionofVIFforasimpleregressionisstraightforward:ifthecorrelationbetweenthe
regressorsishigh,thentheVIFwillbelarge.ThetolerancelevelisthereciprocalofVIF.
Belsley(1991)pointsoutthemaindrawbacksofthesetwomeasures:(1)highVIFsaresufficientbutnot
necessary to collinearity problem, and (2) it is impossible to determinewhich regressors are nearly
dependent on each other by usingVIFs. The thirdmeasure, the condition number, is based on the
eigenvalues of the regressors. Since the condition number avoids the shortcomings of the
aforementionedmethodologies(seeBelsley(1991)andDeMaris(2004)),weusetheconditionnumber
asthecollinearitymeasure.Assumethereisastandardizedlinearsystemy=X+.Denote(kappa)as
theconditionnumberandtheeigenvaluesofXX.TheconditionnumberofXisdefinedas
( ) = maxmin
1.vv
X (3.1)
IfXiswellconditioned(i.e.theregressorcolumnsareuncorrelated),thentheconditionnumberisone,
which impliesthatthevariance isexplainedequallybyalltheregressors.Ifcorrelationexists,thenthe
eigenvaluesarenolongerequalto1.Thedifferencebetweenthemaximumandminimumeigenvalues
willgrowasthecollinearityeffectincreases.AssuggestedbyBelsley(1991),weuseaconditionnumber
of10asameasureofthedegreeofmulticollinearity.2
3.2.3.2Remedyofhighcollinearity
Oncecollinearity isdetected,weneedtoremedytheproblem.ToovercomeOLSparameter instability
duetomulticollinearity,we implementanalternativetothe linearregression, i.e.theridgeregression
technique.Thisestimationprocedurecansubstantiallyreducethesamplingvarianceoftheestimator,
by adding a small bias to the estimator. Kutner,Nachtsheim,Neter and Li (2004) show that biased
estimatorswithasmallvariancearepreferabletotheunbiasedestimatorswithlargevariance,because
2As thereareonly two regressors in theNelsonSiegelmodel,wecanplotaonetoone relationshipbetween theconditionnumber and the correlation between the two regressors. In our dataset, a condition number above 10 is equivalent to acorrelationwithanabsolutevalueabove0.8.
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12
the small variance estimators are less sensitive tomeasurement errors.We therefore use the ridge
regressionandcomputeourestimatesasfollows:
[ ] = + 1* ,k X X I X y (3.2)wherekiscalledtheridgeconstant,whichisasmallpositiveconstant.Astheridgeconstantincreases,
thebiasgrowsand theestimatorvariancedecreases,alongwiththeconditionnumber.Clearly,when
k=0theridgeregressionisasimpleOLSregression.
3.2.3.3Implementation
AspointedoutbyKutneretal.(2004),collinearity increasesthevarianceoftheestimatorsandmakes
the estimated parameters unstable. However, even under high collinearity, the OLS regression still
generatestheunbiasedestimates.Asaresult,weimplementacombinationofthegridsearchandthe
ridgeregressionusingthefollowingsteps:
1. PerformagridsearchbasedontheOLSregressiontoobtaintheestimateofwhichgenerates
thelowestmeansquarederror.
2. Calculatetheconditionnumberfortheoptimal.
3. Reestimatethecoefficientsbyusingridgeregressiononlywhentheconditionnumberisabove
aspecificthreshold(e.g.10).Thesizeoftheridgeconstantischosenusinganiterativesearching
procedure3that finds the lowestpositivenumber, k,whichmakes the recomputed condition
numberfallbelowthethreshold.Byaddingasmallbias,thecorrelationbetweentheregressors
willdecreaseandsowilltheconditionnumber.
4.Dataandmethodology
To illustrateourNelsonSiegel termstructure fittingprocedure,weuseEuriborratesmaturing from1
weekup to12monthsandEuroswap rateswithmaturitiesbetween2yearsand10years.TheEuro
OvernightIndexAverage(EONIA),andthe20,25and30yearEuroswaprateswerealsocollectedto
assess the outofsample prediction quality of the selected estimation procedures. The Euribor and
3Westartwithk=0andweiterativelyrecomputetheconditionnumberafterincreasingtheridgeconstantwith0.001.Westopiteratingwhentherecomputedconditionnumberislowerthantheprespecifiedthreshold(i.e.10).
-
13
EONIA rateswereobtained from theirofficialwebsite,and theEuro swap ratesweregathered from
Thompson DataStream. Our dataset spans the period from January 4, 1999 toMay 12, 2009 and
includes2644days.
Weusethesmoothedbootstraptoconstructthespotratecurves:
1. AstheEuriborrates,R(),withmaturitieslessthanoneyearusesimpleinterestrateswiththe
actual/360daycountconvention,weconvertthemto
( ) ( ) = + 365/1 / 360 ,ActualDaysactualR R Days (4.1)whereR()istheannuallycompoundedEuriborrateusingactual/365dateconvention.
2. Swapratesareparyields,sowebootstrapthezerosrates.DenoteS()astheswaprate,timeto
maturitybeing.Thefollowingequationhelpsustoextractthespotratesfromtheswaprates:
( ) ( ) ( )
=
= +
1/
1
11 1.1
jj
R SR j
(4.2)
Here=2,...,10andtheEuroswapratesusetheactual/365daycountconvention.
3. AstherelationshipbetweenEquation2.1and2.3onlyholdsforcontinuouslycompoundedrates,
weneedtoconverttheannualizedspotratestocontinuouslycompoundedrates:
( ) ( ) = + log 1 .r R (4.3)Table2summarizesthedescriptivestatisticsforthetimeseriesofcontinuouslycompoundedspotrates
weusetofitthespotratecurve.Thetableshowsthatthevolatilityofthetimeseries increasesfrom
0.98%forweeklyratesto1.03%for3monthrates,andthengoesdownto0.69%for10yearspotrate.
Theaveragespotrateincreasesastimetomaturitygrows,from3.16%fortheoneweekrate,to4.53%
fora10yearmaturity.Autocorrelationishighforratesofallmaturities,fromabove0.998witha5day
lagtoabove0.915witha255daylag.
-
14
Table2:DescriptiveStatisticsofSpotRates(RatesAreinPercentage)
Maturity Mean Std.Dev. Min. Max. ( ) 5 ( ) 25 ( ) 255 1Week 3.186 0.982 0.710 5.240 0.998 0.972 0.9261Month 3.238 0.995 0.866 5.257 0.999 0.975 0.9262Months 3.292 1.013 1.111 5.299 0.999 0.980 0.9353Months 3.334 1.030 1.307 5.431 0.999 0.983 0.9414Months 3.351 1.027 1.379 5.441 0.999 0.984 0.9445Months 3.364 1.026 1.435 5.442 0.999 0.984 0.9446Months 3.377 1.025 1.501 5.449 0.999 0.984 0.9457Months 3.388 1.022 1.535 5.448 0.999 0.984 0.9458Months 3.400 1.020 1.566 5.445 0.999 0.984 0.9459Months 3.413 1.019 1.590 5.448 0.999 0.984 0.94410Months 3.426 1.017 1.613 5.444 0.999 0.984 0.94311Months 3.439 1.015 1.636 5.440 0.999 0.983 0.94312Months 3.453 1.014 1.656 5.451 0.999 0.983 0.9422Years 3.568 0.911 1.724 5.435 0.998 0.974 0.9233Years 3.742 0.845 2.160 5.513 0.998 0.972 0.9184Years 3.895 0.796 2.383 5.563 0.998 0.970 0.9155Years 4.029 0.762 2.599 5.614 0.998 0.971 0.9166Years 4.153 0.740 2.729 5.692 0.998 0.971 0.9207Years 4.267 0.726 2.845 5.755 0.998 0.973 0.9258Years 4.369 0.716 2.951 5.820 0.998 0.974 0.9289Years 4.456 0.705 3.047 5.891 0.998 0.975 0.93210Years 4.530 0.696 3.134 5.957 0.998 0.975 0.934Note:Spotratesareexpressedinpercentagewithcontinuouscompounding.ThesampleperiodrunsfromJanuary4,1999toMay12,2009, totaling to2644days.Thespotrateswithmaturities less thanoneyearareretrieved from theEuriborrates,whereasthosewithamaturityofmorethanoneyeararebootstrappedfromEuroswaprates.Bothareconvertedtoobtainrateswithaccordingtotheactual/365(ISDA)dateconvention. ( ) n isthendaylagautocorrelation.
-
Note:This f2009, totalimaturities lbootstrappeconvention.
Figure5p
datasetc
shortterm
0.7% in2
3.134%an
theyieldc
compared
Fig
figureplots theng to2644dayessthanoneyeed from Euro s.
plots the tim
containsa lot
mspotrates
2009,due to
ndalmost6%
curves,while
dtotheSsha
gure5:TimeS
timeseriesof tyswith the folloearareretrievedswap rates. Bo
eseriesofm
tofvariation
(1week)var
the financial
%.Theyieldc
atothertime
apedcurvesin
Seriesofthe
theEurospotraowing times tomdfromtheEuribth are converte
monthlyspot
inthe level,
yfromappro
crisis.The lo
curveismost
estherearet
notherperiod
15
EuroSpotRa
atecurve.Thesmaturity:1weeborrates,whereed to obtain ra
rates in3di
theslopean
oximately3.7
ongtermspo
oftenupwar
troughs.Betw
ds.
ateCurves(1
sampleperiodrek,112monthseasthosewithaates with acco
mensions.W
ndthecurvat
5%to5%in
ot rate is rela
rdsloping.Ar
ween2003an
9992009)
runs from Januasand210yearamaturityofmrding to the a
Wecanclearly
tureofthete
2008,andde
ativelystable
round2006t
nd2005they
ary4,1999 toMrs.Thespot ratemorethanoneyectual/365 (ISDA
yobserve tha
ermstructure
ecreasestoa
e,varyingbet
herearehum
ieldcurveisf
May12,eswithearareA) date
atour
e.The
lmost
tween
mpsin
flatter
-
16
5.EmpiricalComparisonoftheEstimationMethods
Inordertocomparethedifferentestimationmethods,weevaluatetheestimationproceduresbasedon
themean absoluteerrorof their forecastingperformance (theMeanAbsolutePredictionErroror in
shorttheMAPE).Theabsoluteerrorismeasuredinbasispointswhichgivesusagoodindicationofthe
economic importanceof the results. For everyday inour time serieswe estimate theNelsonSiegel
modelbasedontheproposedestimationmethods,i.e.forthegridsearch,theOLSwiththefixedshape
parameterandthegridsearchusingtheconditionalridgeregression.Wethenusetheestimatedterm
structures to forecast the spot rates used in the estimation (insample forecasting) and the
contemporaneous EONIA, 20, 25 and 30year Euro swap rates (outofsample forecasting). The
estimationprocedurewhichproduces(overtheavailabletimeseries)the lowestMAPEswinstherat
race.
5.1TheTimeSeriesoftheEstimatedParameters
First,we discuss the results for the grid search, and subsequentlywe comment on the parameter
estimatesfortheOLSapproachwheretheshapeparameterisfixed.Finally,wepresenttheparameters
forthegridsearchusingtheconditionalridgeregression.
5.1.1Thegridsearch
Figure6graphicallyrepresentsthetimeseriesof0,1,2and(0+1)estimates,basedonagridsearch
usingOLS.Atsomepointsintime,thethreecoefficientsareclearlyquiteerratic.Moreover,forthelong
term interestrate level0,somenegativevaluesareobtained, therebyclearlyviolatinganyeconomic
intuition.Theshortendofthetermstructure,denotedby(0+1),isalwayspositive.Thisisexplained
byhighlynegativecorrelationbetweenthetimeseriesof0and1estimates.ForAugust21,2007e.g.
the high 0coefficient (9.737) is accompaniedwith a low 0 coefficient (5.096)which leads to an
estimateoftheshortrateof5.477%.
-
17
Figure6:TimeSeriesofEstimatedParameterswiththeGridSearchBasedonOLS
Note:Thisfigureplotsthetimeseriesof0,1,2and(0+1)estimatesoftheNelsonSiegelmodelonEurospotratesbasedonagridsearchusingOLSovertheperiodfromJanuary4,1999toMay12,2009.
Inanattempttounderstandthesourceoftheerratictimeseriesbehaviour,wereportthehistogramof
theestimatedshapeparameters (Figure7).Thevariationof the shapeparameterestimates indicates
that thisparametercannotbeassumedconstantover time.Thisconfirms thevisual inspectionof the
timeseriesplotofourdataset(Figure5)whichrevealedthattheshapeandthepositionofthehumps
changedovertime.Morethan55%oftheestimatedshapeparametersarelocatedwithintherangeof0
to2,approximately20%withintherangeof2to4,andalittlemorethan19%withintherangeof8to
01/15/00 05/29/01 10/11/02 02/23/04 07/07/05 11/19/06 04/02/08-5
0
5
10
15
20
25
21-Aug-20079.737
Date
0 (Grid Search Based on OLS)
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-15
-10
-5
0
5
21-Aug-2007-5.095
Date
1 (Grid Search Based on OLS)
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-25
-20
-15
-10
-5
0
5
10
15
21-Aug-2007-7.339
Date
2 (Grid Search Based on OLS)
01/15/00 05/29/01 10/11/02 02/23/04 07/07/05 11/19/06 04/02/081
1.5
2
2.5
3
3.5
4
4.5
5
5.5
6
Date
0 + 1 (Grid Search Based on OLS)
-
10.Forth
boundof
Note:Thisfgridsearchperformedw
Thereare
bound of
hump/tro
4WeperforThe shapesearchinter
heshapepar
thesearchin
Figure7:His
figureshowsthebasedonOLSowiththeshapep
etwoexplana
f the search
ough.Bothsit
rmedgridsearchparameters thatrvalwhenthisup
ameterswith
ntervali.e.at
stogramofO
ehistogramtheoverthesampleparameterrangi
ationsforthe
interval: the
uationsoccu
hwiththeshaptareestimatedpperboundis20
hintherange
10.4
OptimalShape
estimatedshapperiodfromJangfrom0to10
erelatively la
e absence o
rinourdatas
eparameterran tobeat theu0or30.
18
eof8to10,
eParameters
peparametersnuary4,1999to.
rgeamount
f a hump/tr
setasinshow
ngingfrom0topperbound (e.g
472outof5
sUsingGridS
oftheNelsonSoMay12,2009
ofshapepar
rough or the
wninFigure8
10,0to20(nog.10)arealsoe
506areestim
SearchBased
Siegelmodelon9,totalingto264
rameterestim
e presence o
8.
otreported)or0estimatedat th
matedattheu
donOLS
nEurospotrate44days.Gridse
matesattheu
of more than
0to30(notrepheupperbound
upper
susingearchis
upper
n one
ported).of the
-
Figure8
Pa
Note:Thisfparametersclearevidenflexibleeno
Figure8
estimate
ispresent
tobeat t
humpatt
2007.Her
inspection
optimals
boundsha
from the
potential
moreapp
8:TheTermS
anelA(Date
figuredepictsthbasedongridsnceofhump/troughtocapturet
plots the ter
attheupper
ted.Sincethe
theupperbo
theveryend
rethetermst
nshowsthat
hapeparame
apeparamete
NelsonSieg
multicollinea
propriatecand
tructureofS
:May20,200
hetermstructursearch inbothPough.InPanelBtheshapeofthis
m structure
boundofthe
etermstructu
oundof the s
oftheterm
tructureisto
onehumpis
eter iscompu
erestimates.
el specificati
arity. In the l
didatetodesc
potRateson
04)
eofspotratesoPanelAandPanthetermstructustermstructure
onMay20,
esearchinter
uredoesnot
search interv
structure.Fig
oocomplicate
notsufficien
uted tobe10
Intheforme
on to fit the
attercase,a
cribetheterm
19
May20,200
Pane
onMay20,2004nelBarebindingurehasonehume.
2004andon
rval.Inpanel
showahump
al.Theoptim
gure8,Panel
edtobedescr
nttocloselyf
0.Bothexam
ercase,thecu
e curve, wit
more flexibl
mstructure.
04(PanelA)a
elB(Date:Au
4(PanelA)andgat10.InPanempandonetrou
nAugust21,
AofFigure8
p/trough,the
mizationproc
lBdepictsth
ribedbythe
fitthetermst
mples illustrat
urvaturecom
h the additio
lemodelsuc
andAugust2
ugust21,200
August21,200elAthetermstrgh,buttheNels
2007witha
8,thesituatio
eshapeparam
cedure theref
hetermstruc
NelsonSiege
tructureont
teproblems
mponentcans
onal benefit
hasSvensso
1,2007(Pane
07)
07(PanelB).TheructuredoesnosonSiegelmode
a shapeparam
onofMay20,
meterisestim
foreestimate
ctureofAugu
elmodel.Gra
hisday.Agai
resulting inu
simplybedro
of eliminati
on (1994)wil
elB)
eshapeotshowelisnot
meter
,2004
mated
es the
st21,
phical
n,the
upper
opped
ng of
lbea
-
20
Figure9:LongTermSpotRateEstimatesandtheirStandardErrorsGridSearch
Note:Thisfigureplotsthelongtermspotrateestimates(solidline)andtheirstandarderrors(dashedline)basedongridsearchoverthesampleperiodfromJanuary4,1999toMay12,2009,totalingto2644days.TheerraticbehaviouroftheNelsonSiegelmodelbasedongridsearchisillustrated.
Gridsearchnotonlyresults inerratictimeseriesof factorestimates,theprecisionoftheestimates is
alsoverytimevarying.Figure9redraws(asanexample)theestimatesofthelongtermspotrate(solid
line)anditsstandarderrors(dashedline).Whereasthestandarderrorsaresmallattimes,manyperiods
ofturbulenceareshowninwhichthestandarderrorsbecome1%andmore!
5.1.2TheOLSwithfixedshapeparameter
Figure10plotsthetimeseriesoftheestimatedparametersconditionalonafixedshapeparameter.In
the leftcolumnwepresent theestimatesusinga fixedshapeparameterof1.37 (as inDieboldandLi
(2006)),whereasontherightsidethosewithafixedshapeparameterof3(as inFabozzietal.(2005))
aredepicted.Generally,thetimeseriesoftheestimatesarenotasvolatileasthosebasedonthegrid
search and the time series look smoothed. The higher shape parameter, however, results in a less
smoothed timeseriesof theestimated0,1and2.The longterm interest rate level impliedby the
NelsonSiegel model is always positive, and the short end does not show negative interest rate
01/01/00 01/01/02 01/01/04 01/01/06 01/01/080
5
10
15
20
25
0 (
%)
01/01/00 01/01/02 01/01/04 01/01/06 01/01/08
0
1
2
3
4
5
6
7
Sta
ndar
d Er
ror(
%)
0Standard Error
-
21
estimates either. However, the economic interpretation of the coefficients as factors, remains
problematic.Atthestartofourseriese.g.,thelongtermrateisestimatedasbeing4.53%(=1.37)and
5.74%(=3)whereasthe30yearswapratewas4.99%.So,whichshapeparametershouldweconsider
tobethemostappropriate?
Theprecisionoftheestimatesimprovesdramaticallycomparedtothegridsearch.Figure11showsthe
standarderrorsforthelongtermrateusing=1.37.Duringthefinancialcrisis,thestandarderrorwent
uptomorethan35basispoints.Thisisaseriousimprovement,comparedtothestandarderrorsofthe
grid search,where the standard errorswent up to 500 basis points andmore.Whether the shape
parametercanbestbefixedto1.37orto3,however,remainsanopenquestion.Especiallytheresults
for2arequitedifferentforbothchoicesinshapeparameter,ascanbeseeninFigure10.Ourestimates
alsosuggest that theeconomiccharacteristicsofthetimeseriesoftheestimatedcoefficientsmaybe
quitedifferent.RecallthattheNelsonSiegelmodelcanbeinterpretedintermsofathreefactormodel,
theestimated coefficientsbeingweights.Taking thevariabilityof the shapeparameterestimateswe
obtained inourgridsearch intoaccount, itcanbequestionedwhether the timevariation incanbe
ignoredatall!
-
22
Figure10:TimeSeriesofEstimatedParameterswithFixedShapeParameters
Note:Thisfigureplotsthetimeseriesof0,1,2and(0+1)estimatesoftheNelsonSiegelmodelonEurospotratesbasedonfixedshapeparametersof1.37(PanelA)and3(PanelB).ThesampleperiodrunsfromJanuary4,1999toMay12,2009.
01/15/00 05/29/01 10/11/02 02/23/04 07/07/05 11/19/06 04/02/080
1
2
3
4
5
6
7
8
9
10
Date
0 (Diebold and Li)
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1
2
3
4
5
6
7
8
9
10
Date
0 (Fabozzi et al)
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-4
-3
-2
-1
0
1
2
3
4
5
Date
1 (Diebold and Li)
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-4
-3
-2
-1
0
1
2
3
4
5
Date
1 (Fabozzi et al)
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-8
-6
-4
-2
0
2
4
6
8
10
Date
2 (Diebold and Li)
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-8
-6
-4
-2
0
2
4
6
8
10
Date
2 (Fabozzi et al)
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1.5
2
2.5
3
3.5
4
4.5
5
5.5
6
Date
0 + 1 (Diebold and Li)
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1.5
2
2.5
3
3.5
4
4.5
5
5.5
6
Date
0+1 (Fabozzi et al)
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23
Figure11:EstimatesoftheLongTermRateandtheirStandardErrors(=1.37)
Note:Thisfiguredepictstheestimatesofthe longtermrate(0)andtheirstandarderrors(StandardError)basedonafixedshapeparameterof1.37overthesampleperiodfromJanuary4,1999toMay12,2009.
5.1.3Gridsearchwithconditionalridgeregression
Adrawbackoftheridgeregressiontechniqueisthelackofstandarderrors,whichprohibitsanykindof
significance testson theestimatedcoefficients (DeMaris (2004)).However,wecan (visually)examine
thestabilityofthetimeseriesestimates.Figure12againconfirmsthatthetimeseriesof0,conditional
onafixedshapeparameterof3,almostperfectlycoincideswiththegridsearch0,timeseries.A low
shapeparametersmoothestheextremejumpsinthecoefficientsseriesalmostcompletely,whereasthe
ridgeregressiontakesamiddleposition.Whenevercanbefreelyestimated(i.e.whenissufficiently
low), no multicollinearity problems occur and the ridge regression is redundant. Whenever the
correlation between the regressors exceeds our threshold, the ridge regression has a moderate
smoothingeffect.However,thevariation inthecoefficients,e.g.0 inFigure12retainsthestrainsput
onthetermstructure.
01/01/00 01/01/02 01/01/04 01/01/06 01/01/080
1
2
3
4
5
6
7
0 (
%)
01/01/00 01/01/02 01/01/04 01/01/06 01/01/08
0
0.1
0.2
0.3
0.4
Sta
ndar
d Er
ror(
%)
0Standard Error
-
Note:This fregression,periodfrom
Figure13
therights
Theestim
Thereare
leveljump
reached i
Ridgereg
longterm
shortend
Figure12:Th
figureplots thefixed shapepar
mJanuary4,1999
showstheti
sidetheresul
matesfromth
enonegative
pedupfrom
tspeakof8
ression impro
minterestrate
oftheterms
heEstimated
estimated longrameterof1.379toMay12,200
meseriesof
ltsfromboth
heridgeregre
evalues inth
4.80%inJune
.99% inOcto
ovesthestab
elevelcompl
structureaga
LongTermR
g term ratesbas7 (DieboldandL09.
alltheestim
thegridsear
essionaremo
e longterm
e2007to5.8
ober2008.Af
bilityofthee
lieswiththe
ainisalwaysp
24
RateBasedon
sedon the folloLi),and fixed sh
atedcoefficie
rchbasedon
orestablecom
interestrate
85%inAugust
fterwards the
estimatescalc
economicint
positive,cons
nAlternative
owingestimationhapeparameter
entsusingth
OLSandther
mparedtoth
levelanymo
t2007,then8
e longterm i
culatedbyth
tuitionbehind
sistentwithre
eEstimationM
nmethods: theof3 (Fabozzie
eridgeregre
ridgeregress
heresultsfro
re.The long
8.14%inMar
interest rate
hegridsearch
dtheNelson
eality.
Methods
gridsearch, theetal.)over the s
ession,where
ionareplotte
mthegridse
term interes
rch2008,and
levelwentd
h.Andthepo
Siegelmode
e ridgesample
eason
ed.
earch.
strate
dthen
down.
ositive
el.The
-
25
Figure13:EstimatedParameterswiththeRidgeRegressionandGridSearch
Note: This figure depicts the estimated parameters of theNelsonSiegelmodel based on both grid search (line) and ridgeregression(dot).0representsthelongterminterestratelevelimpliedbytheNelsonSiegelmodel.0+1representstheshortterminterestratewhentimetomaturityiszero.
Inordertomeasurethestabilityofthetimeseriesofestimatedcoefficientsmoreformally,wecompute
thestandarddeviationoftheirfirstdifferences(Table3).Wenoticethatridgeregressionshavealower
volatility forall threeparameters.Moreover,anFtestat the95%confidence intervalshows that the
standard deviations of the ridge regression coefficients changes are significantly lower than those
obtainedthroughthegridsearch.Theridgeregression,hence,cansubstantiallyreducetheinstabilityof
the estimates in the grid search. Compared with the fixed shape parameter procedures, the ridge
regressionallows theshapeparameter tovaryover time.Whetherornot this isadesirableproperty
fromaneconomicpointofview,stillhastobeseen.Therefore,weexaminetheinandoutofsample
predictionperformanceofthevariousmethods.
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0
5
10
15
20
25
Date
0 (Ridge vs Grid Search)
Grid Search Based on OLS
Ridge Regression
01/15/00 05/29/01 10/11/02 02/23/04 07/07/05 11/19/06 04/02/08-20
-15
-10
-5
0
5
Date
1 (Ridge vs Grid Search)
Grid Search Based on OLSRidge Regression
01/15/00 05/29/01 10/11/02 02/23/04 07/07/05 11/19/06 04/02/08-30
-25
-20
-15
-10
-5
0
5
10
15
Date
2 (Ridge vs Grid Search)
Grid Search Based on OLSRidge Regression
01/15/00 05/29/01 10/11/02 02/23/04 07/07/05 11/19/06 04/02/081
1.5
2
2.5
3
3.5
4
4.5
5
5.5
6
Date
0 + 1 (Ridge vs Grid Search)
Grid Search Based on OLSRidge Regression
-
26
Table3:TheStandardDeviationsofFirstDifferencesintheEstimates(inPercentage)
GridSearch RidgeRegression =1.37 =30 0.602 0.141 0.058 0.0791 0.584 0.138 0.068 0.0802 1.594 1.106 0.126 0.225
Note:Thistableshowsthestandarddeviationsofthefirstorderchangesinthetimeseriesoftheestimatedparameters.Thedatasetusedtoestimatetheparametersiscomposedof1week,1to12month,and1to10yearspotrates.AnFtestata95%confidenceintervalshowsthatallthestandarddeviationsaresignificantlydifferentfromeachother.
5.2Insampleperformance
Inorder toexamine the insampleperformance,wecompute themeanabsoluteerrorsbetween the
predictedand thebootstrappedspot rate (Table4).To testwhetherMAPEsarestatisticallydifferent
fromeachother,wecompute:
1 2 ,Method Method = 1 r r r r i (5.1)
wherer isthevectorofempiricalratesforacertaintimetomaturity,1 isavectorofones, 1Methodr and
2Methodr arethevectorsofestimatedspotratesusingdifferentmethods(e.g.grid,ridge,DieboldandLi(DL)andFabozzietal. (FMP)). Iftheestimatedcoefficient issignificantlynegative,thenweconsiderMethod1tobebetterthanMethod2.TheNeweyWestcorrectionisusedtoremoveserialcorrelation
fromtheresiduals.
AlthoughtheoverallMAPEisminimizedbyconstructionfortheGridSearch,theinsampleMAPEsper
maturity show how the fixed shape parametermethods perform compared to the ridge regression
technique.TheMAPEofFMP(DL)isfor13(9)outofthe22maturitiesthehighest.For8outofthe22
maturities,theridgeregressiongeneratesthelowestMAPE,butitneverproducesthehighestMAPEs.
Thegrid search is formore thanhalfof thematurities theMAPEminimizingmethod.The insample
MAPEs reveal the limitationsof reducing themodel flexibilityby fixing the shapeparameters.Ridge
regressionoutperformsthesetwomethodsconvincingly.
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Table4:InSampleMeanAbsolutePredictionErrors
Maturity Grid Ridge DL(=1.37) FMP(=3)1Week 0.113 0.103* 0.130 0.170+1Month 0.067 0.059* 0.076 0.114+2Months 0.035 0.031* 0.033 0.062+3Months 0.031* 0.035 0.034 0.042+4Months 0.030* 0.034 0.036+ 0.0345Months 0.031* 0.035 0.039+ 0.0366Months 0.033* 0.035 0.043 0.047+7Months 0.033* 0.034 0.043 0.055+8Months 0.034* 0.034 0.044 0.063+9Months 0.035 0.035* 0.045 0.070+10Months 0.036 0.035* 0.045 0.075+11Months 0.038 0.037* 0.045 0.079+12Months 0.041 0.039* 0.046 0.083+2Years 0.055* 0.068 0.073+ 0.0573Years 0.048* 0.065 0.077+ 0.0554Years 0.033* 0.052 0.072+ 0.0655Years 0.028* 0.044 0.065+ 0.0616Years 0.024* 0.030 0.046 0.047+7Years 0.015 0.013* 0.017 0.026+8Years 0.013 0.018 0.022 0.008*9Years 0.020* 0.037 0.054+ 0.03410Years 0.033* 0.055 0.083+ 0.066Note: InsamplemeanabsoluteerrorsbetweenproduceddatafromtheNelsonSiegelandempiricaldataarepresented.Thedatasetusedtoestimatetheparametersiscomposedby1week,1to12month,and1to10yearspotrates.*ThisapproachyieldsthelowestMAPEforthistimetomaturity.+ThisapproachyieldsthehighestMAPEforthistimetomaturity.Exceptthefollowingpairs,alltheMAPEsaresignificantlydifferentfromeachother(at95%confidenceinterval)basedonthettestwithNeweyWestcorrectedstandarderrors:2month:gridandDL;3month:ridgeandDL;4month:ridgeandFMP;5month:ridgeandFMP;2year:gridandFMP;5year:DLandFMP;6year:DLandFMP;9year:ridgeandFMP.ThemeanabsoluteerrorsaretestedusingEquation5.1.
5.3Outofsampleperformance
SincetheridgeregressionaddsasmallbiastotheOLS,weconsideranoutofsampleperformancetest
superior in order to judge the appropriateness of the various estimation methods. If we denote
lr r = as the residualbetween thespot rate r observed from themarketand theestimatedspotratebytheNelsonSiegelmodel lr foracertaintimetomaturity,thebiasisestimatedastheaverageofthes.Theoutofsamplebiasoneachday ismeasuredbyaveragingtheresidualsafterfittingthe
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EONIA, 20, 25 and 30year swap rates using four methods. Table 5 clearly shows that the bias
introducedintheridgeregressiondoesnotaffectthebiasintheforecastedspotratesinamaterialway
comparedtotheotherestimationmethods.
Table5:OutofSampleBias
Grid Ridge DL(=1.37) FMP(=3)
Mean 0.070 4.00E4 0.099 0.089
Std.Dev. 0.384 0.152 0.102 0.214
Minimum 2.216 0.925 0.356 0.820
Maximum 0.703 0.369 0.393 0.558
Note:Thebiasisexpressedinpercentage.ThesampleperiodrunsfromJanuary4,1999toMay12,2009,totalingto2644daysforwhich theoutofsampleestimationbias ismeasured.Theoutofsamplebiasoneachday ismeasuredbyaveraging theresidualsafterfittingtheEONIA,20,25and30yearswapratesusingfourmethods.AllthebiasesaresignificantlydifferentfromeachotherbasedonattestwithNeweyWestcorrectedstandarderrors.
To investigate the ability of these four approaches to forecast the long and short end of the term
structure,wewillcomparetheestimatedratestotheEONIA,the20,25and30yearEuroswaprates.
TheMAPEwillagainbeourcriterion.
Theoreticallyspeaking,theestimated0+1representstheshortendofthetermstructure.However,
theEONIAratesaretheshortesttermspotratesthatcanbeobservedinthemarket.Consequently,ifa
modelcanpredicttheEONIArateswiththehighestaccuracy,itwillbesuperiorinpredictingtheshort
endoftheyieldcurve.
TheestimatedEONIAratesarecalculatedbypluggingtimetomaturity=1/365intoEquation2.3along
with the estimated parameters for all fourmethodologies.Afterwards, the differences between the
empirical and the estimated rates are examined following the same procedure as for the insample
MAPEstests.
Inaddition,wealsocheckwhichmodelcanbestfitthelongtermendofthetermstructure.However,
longtermspotratesarenotdirectlyobservableinthemarketeither.Moreover,duetothelackofswap
ratesforcertaintimestomaturity(e.g.11or29yearswaprate)tobootstrapthe longtermspotrate
(e.g.30yearspotrate),wewillusethefollowingproceduretochecktheforecastingability:
1. CombiningEquation2.3and3.4,wecalculatetheestimatedswapratesusing
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29
( ) ( )( )1
1 1,
1
1j
j
RS
R j
=
+ = +
(5.2)
where=2,...,30arethetimestomaturity,
( ) ( ) 1rR e =
is the estimated year annually compounded spot rate, ( )r is the estimated continuouslycompoundedspotrate,and ( )S istheestimatedswaprate.
2. Wecalculateand test theMAPEsbetween theempiricaland theestimated swap ratesusing
thesameprocedureaspreviously.
TheresultsaresummarizedinTable6.TheridgeregressionalwaysyieldsthestatisticallylowestMAPEs.
TherestrictionDLandFMPputontheshapeparametermakesthemunderperformcomparedtoboth
the ridge and theOLS regression.Moreover, the ridge regression has lower prediction errorswhen
predictingthelongend,comparedtotheshortendofthetermstructure.
Table6:OutofSampleMeanAbsolutePredictionErrors
Maturity Grid Ridge DL(=1.37) FMP(=3)OvernightEONIA 0.254 0.246* 0.287+ 0.27820yearswaprate 0.201 0.142* 0.234+ 0.22125yearswaprate 0.262 0.150* 0.236 0.268+30yearswaprate 0.304 0.152* 0.227 0.307+Note:OutofsampleMAPEsbetweenproduceddatafromNelsonSiegelandempiricaldataarepresented.Thedatasetusedtoestimate theparameters is composedby1week,1 to12month,and1 to10year spot rates.*Thisapproach yields thelowestMAPEforthistimetomaturity.+ThisapproachyieldsthehighestMAPEforthistimetomaturity.Exceptthefollowingpairs,alltheMAPEsaresignificantlydifferentfromeachother(at95%confidence interval)basedonthettestwithNeweyWestcorrectiononstandarderrors:20year:gridandFMP,DLandFMP;25year:DLandFMP,gridandFMP;30year:gridandFMP.ThemeanabsoluteerrorsaretestedusingEquation5.1.
The superiority of the ridge regression procedure is not only statistically significant. Looking at the
MAPEsforthe30yearswaprate,theMAPEsareloweredwith7to15basispoints.Ontheshortend,
thegainismoremoderate,upto4basispoints.
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5.4Robustnesscheckontheforecastingability
Weconsidertworobustnesscheckstoconfirmtheoutperformanceoftheconditionalridgeregression
procedurewepropose. First,wewant to verifywhetherornotour results aremainlydrivenby the
20082009financialcrisiswhichispartofourdataset.Second,wehaveshownthatthemulticollinearity
problemisseverelyaffectedbythechoiceofthematurityvector.Wewillexaminewhetherourresults
arerobusttothechoiceofadifferentmaturityvector.
5.4.1Theimpactofthefinancialcrisis
AsseeninFigure13,thefinancialcrisishashadasubstantialimpactonparameterestimation.Wethus
divideourdataset into two subsets, theprecrisisperiod from January4,1999 to July2,2007 (2169
days),andthecrisisperiodfromJuly3,2007toMay12,2009(475days).Theoutofsamplepredicting
powerofallfourapproaches(Grid,Ridge,DLandFMP)ispresentedinTable7andTable8.
AttestbetweentheprecrisisandcrisisperiodMAPEsat95%confidence levelshowsthatduringthe
financialcrisisthepredictingabilityofallfourmethodsissignificantlylowered.Thepredictingabilityof
thegridsearchdropsdramaticallyforboththeshortandthe longendofthetermstructure,whilefor
theothermethodologies,thefinancialcrisishasmoreimpactontheshortendthanonthelongend.
Nevertheless, theridgeregressionperformsconsistently inbothperiods,while thegridsearchclearly
doesnot.Duringthefinancialcrisisthegridsearchpredictionsareworstforthe longendoftheyield
curvewhereasintheprecrisisperiod,theFMPmodelisworstforthesematurities.
Theresultsshowninthesetwotablesagainconfirmourpreviousfindingsthattheridgeregressionhas
superiorpredictabilityinforecastingbothendsoftheyieldcurve.
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Table7:OutofSampleMeanAbsolutePredictionErrors(PrecrisisPeriod)
Maturity Grid Ridge DL(=1.37) FMP(=3)OvernightEONIA 0.161 0.161* 0.195+ 0.16920yearswaprate 0.142 0.137* 0.206 0.217+25yearswaprate 0.161 0.140* 0.218 0.260+30yearswaprate 0.169 0.131* 0.211 0.296+Note:OutofsampleMAPEsbetweenproduceddata fromNelsonSiegelandempiricaldataarepresented for theprecrisisperiodfromJanuary4,1999toJuly2,2007(2169days).Thedatasetusedtoestimatetheparametersiscomposedby1week,112month,and1to10yearspotrates.*Thisapproachyieldsthe lowestMAPEforthistimetomaturity.+ThisapproachyieldsthehighestMAPEforthistimetomaturity.Exceptthefollowingpairs,alltheMAPEsaresignificantlydifferentfromeachotherbasedonthettestwithNeweyWestcorrectiononstandarderrors:EONIA:gridandridge,gridandFMP,ridgeandFMP;20year:gridandridge,DLandFMP.
Table8:OutofSampleMeanAbsolutePredictionErrors(CrisisPeriod)
Maturity Grid Ridge DL(=1.37) FMP(=3)OvernightEONIA 0.676 0.635* 0.704 0.775+20yearswaprate 0.470+ 0.165* 0.363 0.24025yearswaprate 0.721+ 0.198* 0.317 0.30630yearswaprate 0.919+ 0.251* 0.296 0.361Note:OutofsampleMAPEsbetweenproduceddatafromNelsonSiegelandempiricaldataarepresentedforthecrisisperiodfromJuly3,2007toAugust12,2009(475days).Thedatasetusedtoestimatetheparameters iscomposedby1week,112month,and1to10yearspotrates.*ThisapproachyieldsthelowestMAPEforthistimetomaturity.+ThisapproachyieldsthehighestMAPEforthistimetomaturity.Exceptthefollowingpairs,alltheMAPEsaresignificantlydifferentfromeachotherbasedonthettestwithNeweyWestcorrectiononstandarderrors:EONIA:gridandDL;20year:gridandDL;25year:DLandFMP;30year:ridgeandDL,DLandFMP.
5.4.2ADifferentMaturityVector
Inordertotesttherobustnessofourresults,weestimatetheyieldcurvesagainusingonly1week,6
month,1to10yearspotrates.Theresults,showninTable9,alsoconfirmourpreviousfindingsthatthe
ridgeregressionhassuperiorpredictabilityinforecastingbothendsfortheyieldcurve.However,unlike
fortheotherdataset,nowthepredictabilityofFMPon25and30yearswapratesisnottheworst,but
the grid search is.Here the correlationbetween the slope andhump factorusing theDLestimation
recipe is0.35 insteadof0.55.ThehighestMAPEsforthe25and30yearswapratesobtainedusing
thegridsearchbasedontheOLSregression,canbeblamedontheinstableestimates.
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Table9:OutofSampleMeanAbsolutePredictionErrors
Maturity Grid Ridge DL(=1.37) FMP(=3)OvernightEONIA 0.293 0.217* 0.255+ 0.24320yearswaprate 0.171 0.128* 0.205+ 0.17925yearswaprate 0.226+ 0.140* 0.207 0.22230yearswaprate 0.266+ 0.147* 0.200 0.259Note:OutofsampleMAPEsbetweenproduceddatafromNelsonSiegelandempiricaldataarepresented.Thedatasetusedtoestimate theparameters is composedby1week,6month,and1 to10year spot rates.*Thisapproachyields the lowestMAPEforthistimetomaturity.+ThisapproachyieldsthehighestMAPEforthistimetomaturity.Exceptthefollowingpairs,alltheMAPEsare significantlydifferent fromeachotherbasedon the ttestwithNeweyWest correctionon standarderrors:EONIA:gridandDL;20year:gridandFMP;25year:gridandDL,gridandFMP,DLandFMP;30year:gridandDL.
Again,we test the influenceof the financialcrisison theperformanceof theproposedmethods, this
timeonourlimitedsample.Theresultsfromthisanalysiscomparingestimatesoftheprecrisisandcrisis
periodaresummarizedinTable10andTable11.
At the95% confidence level,a ttestbetween theprecrisisand crisisperiodMAPEs shows that the
performanceofthefourmethodsbehavessimilartothatoftheotherdataset.Thehighvolatilityofthe
estimatesinthegridsearchmakesitsperformancedropsubstantiallyduringthefinancialcrisis.
Theridgeregressionalwayshas thehighestpredictingabilityexcept for the30yearswaprateduring
thecrisisperiod,wheretheDLhasthehighestpredictingability.However,thedifferencebetweenthese
twomethodsforthe30yearswaprateduringthefinancialcrisisisnotstatisticallysignificant.
Table10:OutofSampleMeanAbsolutePredictionErrors(PrecrisisPeriod)
Maturity Grid Ridge DL(=1.37) FMP(=3)OvernightEONIA 0.216+ 0.156* 0.186 0.16020yearswaprate 0.128 0.120* 0.191+ 0.17325yearswaprate 0.150 0.124* 0.201 0.209+30yearswaprate 0.161 0.121* 0.192 0.242+Note:OutofsampleMAPEsbetweenproduceddata fromNelsonSiegelandempiricaldataarepresented for theprecrisisperiodfromJanuary4,1999toJuly2,2007(2169days).Thedatasetusedtoestimatetheparametersiscomposedby1week,6month,and1to10yearspotrates.*ThisapproachyieldsthelowestMAPEforthistimetomaturity.+ThisapproachyieldsthehighestMAPEforthistimetomaturity.Exceptthefollowingpairs,alltheMAPEsaresignificantlydifferentfromeachotherbasedonthettestwithNeweyWestcorrectiononstandarderrors:25year:DLandFMP.
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Table11:OutofSampleMeanAbsolutePredictionErrors(CrisisPeriod)
Maturity Grid Ridge DL(=1.37) FMP(=3)OvernightEONIA 0.642+ 0.499* 0.571 0.62420yearswaprate 0.365+ 0.164* 0.268 0.20525yearswaprate 0.578+ 0.213* 0.236 0.28030yearswaprate 0.749+ 0.264 0.236* 0.337Note:OutofsampleMAPEsbetweenproduceddatafromNelsonSiegelandempiricaldataarepresentedforthecrisisperiodfromJuly3,2007toAugust12,2009(475days).Thedatasetusedtoestimatetheparametersiscomposedby1week,6month,and1 to10year spot rates.*Thisapproachyields the lowestMAPE for this time tomaturity.+Thisapproach yields thehighestMAPE for this time tomaturity.Except the followingpairs,all theMAPEsaresignificantlydifferent fromeachotherbasedonthettestwithNeweyWestcorrectiononstandarderrors:EONIA:gridandDL,gridandFMP;25year:ridgeandDL,DLandFMP;30year:ridgeandFMP.
One thingworthmentioning is that for the alternative dataset, not only the long end of the term
structurebasedonthegridsearchisextremelyvolatileandsometimesnegative,soistheshortendof
thetermstructure,asshowninFigure14.Thisagainshowsthatthegridsearchisverysensitivetothe
underlyingdataset.
Figure14:TheShortEndoftheTermStructurebytheGridSearchBasedonOLS
Note:ThisfigureplotstheshortendofthetermstructureimpliedbythegridsearchedbasedonOLSoverthesampleperiodfromJanuary4,1999toMay12,2009,totalingto2644days.
01/15/00 05/29/01 10/11/02 02/23/04 07/07/05 11/19/06 04/02/08-20
-15
-10
-5
0
5
10
15
20
25
30
Date
0 + 1 (Grid Search Based on OLS)
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6.Conclusion
Many researchers have reported problems in estimating the NelsonSiegel (1987)model.We have
shown thatmulticollinearity between the slope and hump factor are causing both instability of the
regressioncoefficientsovertimeandlargestandarderrorsonthecoefficients.Totempertheestimation
problems,weapplyridgeregressiontechnique,wheneverthegridsearchbasedestimateoftheshape
parameter results in highly correlated slope and hump factors. For euro spot rate curves, over the
period1992009,wecomparethegridsearchestimatesoriginallyproposedbyNelsonandSiegelto
ourridgeregressionestimates.TheDieboldandLi(2006)andtheFabozzietal.(2005)estimateswere
alsocalculatedasabenchmark.
The insample comparison shows that the grid search produces erratic time series estimateswhich
sometimesviolatetheeconomicintuitionbehindtheNelsonSiegelmodel.Thedistributionofthefreely
estimatedshapeparametersandthe insamplefittingerrorsrevealthe limitationoftheuseofafixed
shapeparameter.Theoutofsamplepredictabilityatthetwoendsofthetermstructureshowsthatthe
ridgeregressionalwaysproducesthe lowestmeanabsolutepredictionerrors.Forthe longendofthe
termstructure,theeconomicgain intheMAPEmountedupto15basispoints.Fortheshortend,the
differencesinMAPEswerestatisticallysignificantbuteconomicallysmaller.
Robustnesschecksshowthattheridgeregressionperformsrobustlyandconsistentlybetterindifferent
economicenvironments (precrisisandcrisisperiod)andwithdifferentchoicesof thematurityvector
(i.e.thesetoffinancialinstrumentsusedtobootstraptheyieldcurve).
Basedonourfindings,fixingtheshapeparameterinordertoavoidmulticollinearity,isastatisticaltrick
thatdoesreducethecorrelationbetweentheregressorswhenthefixingisjudiciallychosen.Ithowever
ignoresthebarefactthat inpractice,termstructuresdotakeallkindof(humpy)shapesandthatthe
humpsimply isnot fixedover the time tomaturityspectrum.The loss in flexibilitycomesatasevere
priceespeciallyforthepredictionsof longtermspotrates.Thispaperadvancesaprocedurebasedon
ridgeregressiontoreducethepredictionerrorssignificantly.
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35
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