Hedge fund leverage and performance: New evidence from...
Transcript of Hedge fund leverage and performance: New evidence from...
Hedge fund leverage and performance: New evidence from multiple leveraged share classes1
Pekka Tolonen
Abstract
This study examines hedge funds’ ability to enhance their performance through
leverage. Using a hand-collected sample of fund leverage classes gathered from major
commercial databases, we find that the use of leverage enhances risk-adjusted returns
and risk. The average high-leverage share class underperforms its low-leverage
counterpart for the same investment program after their returns are appropriately
adjusted to the same level. The portfolio being long low-leverage share classes and
short high-leverage share classes constructed to be market neutral, provides positive
and significant risk-adjusted performance during the 1994 – 2012 time period. This
finding is consistent with the theoretical predictions of Frazzini & Pedersen (2013)
and Black (1972) and indicates that leverage constraints and costs of leverage have a
negative impact on risk-adjusted returns.
1 We thank Robert Kosowski and Juha Joenväärä for helpful comments. We thank Mikko Kauppila for help with the data. We are grateful for the support of OP-Pohjola Group Research Foundation. Contact address: Pekka Tolonen, University of Oulu, [email protected].
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1 Introduction
This study examines hedge funds’ ability to enhance their performance through
leverage. Hedge fund management companies often have multiple share classes of the
same investment program, which only differ in their leverage levels. Using a hand-
collected data for levered share classes constructed from the union of major
commercial databases, we show that management companies establish high-leverage
classes of their investment programs that exhibit higher levels of total returns and
volatility. We show that the average high-leverage class of the investment program
underperforms its low-leverage counterpart after the returns (and the risk) of both
classes are adjusted to the same level. Our findings are in line with the theory of
leverage aversion (Frazzini & Pedersen 2013, Asness et al. 2012, Black 1972) and
suggest that costs of leverage and leverage constraints of investors have a negative
impact on returns. The high-leverage classes generate economically and statistically
significant alpha but not to the extent that could be expected based on their level of
leverage.
Leverage is one of the important drivers of returns in hedge fund industry, which
currently manages over $2 trillion of assets. Hedge funds use leverage to exploit
investment opportunities and attain a level of volatility desired by investors. Hedge
funds obtain leverage through direct financing, margin borrowing (e.g., shorting),
derivative transactions (options, futures, etc.), structured products, and repurchase
agreements (REPOs). After the experience of the recent financial meltdown in 2008,
many hedge funds saw their borrowing abilities reduced. For example, the blow-up of
Bearn Stearns’ two structured credit strategy funds in 2007 increased concerns over
the risks associated with high leverage. In December of 2007, the Wall Street Journal2
reported that
Investment banks are cutting back on loans to hedge funds, eliminating some
clients and raising borrowing fees for others. The lenders are slimming their
balance sheets after heavy losses in the debt markets in recent months. And,
after multi-billion-dollar write-downs, they also are becoming more cautious
as the economy slows.
Hedge funds are, therefore, often limited in their use of leverage. Dai & Sundaresan
(2010) show theoretically that hedge funds have "short positions" to two different
2 Gregory Zuckerman and Alistair MacDonald, “Hedge funds feeling pinch on credit”, Wall Street Journal, 28 December 2007.
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options: (1) the ability of prime brokers to increase margin requirements in the bad
states of the world and withdraw credit lines (funding option); (2) investors are
willing to withdraw their investments in the bad states of the world (redemption
option). Their model predicts that both risk factors may restrict even good managers’
abilities to use leverage. In the model of Liu & Mello (2011), the fragile nature of the
capital structure, combined with low market liquidity, creates a risk of coordinated
redemptions among investors that severely limits hedge funds’ arbitrage capabilities.
The risk of coordination motivates managers to behave conservatively.
Gârleanu & Pedersen (2011) argue that funding problems have important asset-
pricing effects. The most extreme situation is the failure of the Law of One Price
suggesting that securities with (nearly) identical cash flows trade at different prices.
Frazzini & Pedersen (2013) show theoretically that if investors are leverage
constrained, low-beta assets have higher risk-adjusted returns than high-beta assets
since investors tend to tilt their portfolios towards high-beta assets. This implies that
high-beta assets do not generate as high returns as predicted by the CAPM (Black et
al. 1972). Frazzini & Pedersen (2013) suggest that this stylized fact is better explained
by the CAPM with restricted borrowing (Black 1972), and they show global evidence
across equities and bonds. Similarly, using a dataset of equity and index options as
well as levered ETFs3, Frazzini & Pedersen (2012) show that portfolios with long
low-embedded-leverage assets and short high-embedded-leverage assets and
constructed to be market neutral, earn statistically significant abnormal returns. The
main point is that embedded leverage alleviates investors' leverage constraints, and
therefore, embedded leverage lowers required returns.
Inspired by these theoretical innovations and empirical findings, this study
examines the performance of hedge fund investment programs which offer multiple
leverage share classes for investors. This allows us to test direct predictions of
leverage aversion theories based on our hedge fund data. In contrast to Frazzini &
Pedersen (2012), who examine embedded leverage with hypothetical portfolios
consisting of individual option contracts or passively managed portfolios (ETFs), our
study provides a novel perspective by examining financial intermediaries with highly
active mandates. As sophisticated market participants, one of the important functions
of hedge funds is to provide leveraged strategies for investors. It is a fundamental
question of whether hedge funds are able to lever their portfolios’ exposures at the
3 A derivative security, for instance, a stock option has embedded leverage which measures security’s return magnification relative to the return on the underlying asset. For equity options, the embedded leverage is measured as: Delta*Stock price / Option price. Similarly, if a levered ETF has a 2-times exposure to S&P 500, the ETF’s embedded leverage is 2.
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level as suggested by their strategies. Our dataset contains strategies that are not
examined in Frazzini & Pedersen (2012) including relative value funds and
directional traders (e.g. CTA) which trade futures. Currently, based on our
knowledge, there are no studies done that would examine the effects of leverage on
hedge fund performance within investment programs.
Empirically, the study closest to ours is Ang et al. (2011). They track hedge fund
leverage over the period from December 2004 to October 2009 in a cross-section of
208 hedge funds using a unique dataset provided by a fund-of-fund. They focus on
economy-wide factors of leverage and show that decreases in funding costs and fund
return volatilities forecast increases in hedge fund leverage. Hedge funds’ leverage
declined during the years 2007 – 2009 suggesting that hedge funds were, at least
partly, able to forecast financial crises and higher costs of borrowing. We differ from
Ang et al. (2011) by examining performance differences of the high- and low-
leverage classes within investment programs.
We collect a dataset of levered hedge fund share classes from the union of five
major databases by checking manually indicators of leverage (e.g., “1X”, “2X”) based
on the names of share classes.4 We identify investment programs that contain at least
two share classes with different levels of leverage and find 362 unique share classes
for the January 1994 – December 2012 study period. The main idea in this study is to
compare the performance of a high-leverage class to its low-leverage counterpart
within each of the investment programs. Our dataset allows us to examine the effects
of leverage on performance and risk within a specific trading program.
In the first part of the empirical analysis, we form equal-weighted (EW)
portfolios of the low- and high-leverage share classes. Our findings show that the
average high-and low-leverage class adds value for investors in terms of risk-adjusted
returns. The results are consistent with Joenväärä et al. (2014a, 2014b) and the related
literature (e.g., Brown et al. 1999, Kosowski et al. 2007, Fung et al. 2008) which
provide evidence of positive risk-adjusted performance among hedge funds. We find
that the high-leverage portfolio has a higher average excess return and a standard
deviation of excess return as well as a higher overall systematic risk than the low-
leverage portfolio. The high-leverage portfolio generates higher (14.79%) annualized
Fung & Hsieh (2004) (hereafter, FH alpha) alphas than the low-leverage portfolio
(6.10%). The EW spread alpha between the high- and low-leverage portfolio is
4 We use the union of five commercial hedge fund databases including Lipper TASS, Hedge Fund Research, BarclayHedge, EurekaHedge, and Morningstar.
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statistically and economically significant 8.69% (t = 5.65) per annum. 5 Both
volatilities and the FH model’s estimated factor loadings are about twice as large for
the high-leverage portfolio suggesting that leverage magnifies both return and risk in
hedge fund portfolios. The high-leverage portfolio has a slightly higher Sharpe ratio,
but we find that the associated p-value of the difference in Sharpe ratios between the
high- and low-leverage portfolios is not statistically significant.6 Therefore, the high-
and low-leverage portfolios seem to exhibit similar risk-adjusted performance after
average excess returns are adjusted with volatility. Overall, our findings suggest that
hedge funds’ use of leverage contributes positively to the value added during the 1994
– 2012 time period.
The dataset also allows a direct test of the leverage aversion theory because the
data contains investment programs with multiple leverage class structures. We
construct three EW portfolios: (1) the portfolio of low-leverage classes; (2) the
portfolio of high-leverage classes; and (3) the spread portfolio being long low-
leverage share classes and short high-leverage share classes with appropriately
adjusted returns.7 The spread portfolio (3) is constructed similarly as the betting-
against-beta (BAB) portfolios of individual options and ETFs in Frazzini & Pedersen
(2012). The economic and practical relevance of the BAB factor using fund share
classes is questionable, since it is not feasible to short hedge funds. We term the
spread portfolio (3) as the relative leverage spread (RLS) portfolio of which the main
purpose is to test statistically the difference in performance and risk between the
portfolios of low- and high-leverage share classes. Intuitively, if hedge funds use
leverage as indicated in their strategies, the RLS portfolio performance should be
statistically indistinguishable from zero. Alternatively, if costs of leverage (and
leverage aversion) have negative effects on performance, the RLS performance is
positive and statistically significant which we find from the data.
We construct a case study and examine performance of 1X- and 2X-classes of the
CTA strategy managed by Ramsey Quantitative Systems, Inc. during the period of
5 If returns are adjusted for backfill-bias by excluding the first 12 months of return history from each share class, the high-leverage portfolio outperforms by 8.99% per annum (14.15% versus 5.16%). The backfill-bias has therefore less than 1% impact on both portfolios’ annual alphas. Intuitively, the backfill-bias should have a similar effect on the low- and high-leverage classes of the investment program because both classes have equally long return histories. 6 We apply the methodology of Ledoit & Wolf (2008) to test the difference in Sharpe ratios between the low- and high-leverage portfolios. 7 Specifically, within each of the investment programs we adjust returns of the high-leverage class to the same level with low-leverage class. If an investment program includes, for instance, a 2X-class and a 4X-class, we divide each monthly return of the 4X-class by 0.5 in order to get the return to the same level with the 2X-class.
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June 2003 – June 2010. The 2X-class with an unadjusted exposure has higher total
returns than the 1X-class (8.1% versus 4.9%). The 2-times leverage increases the total
risk by 2 (6.4% volatility * 2 = 12.8%). The 2X-class with adjusted market exposure,
however, underperforms the 1X-class consistently over the time period. On average,
the difference in total returns is 90 basis points (4.0% versus 4.9%). This examination
highlights the costs of leverage on performance of an investment program.
The RLS portfolio consists of EW returns of individual low- and high-leverage
classes. It provides a statistically significant FH alpha for the January 1994 –
December 2012 study period. The FH alpha of the spread portfolio is 1.63% per
annum (t = 5.47). This suggests that the average high-leverage class on the short-side
of the spread portfolio (with adjusted market exposure) generates a 1.63% lower alpha
than the average class on the long-side of the spread portfolio consisting of the low-
leverage classes. The EW portfolio of the high-leverage classes with adjusted returns
generates also lower Sharpe ratios (0.96 versus 1.17). Although the high-leverage
class generates economically and statistically significant alpha which investors can
exploit, the alpha is not as high as indicated based on their use of leverage. The
statistically and economically significant spread in the FH alpha between the
portfolios of low- and high-leverage classes is robust to backfill-adjustment, an
inclusion of fund-of-funds, and a sub period analysis.
It is important to control for effects of fees. Intuitively, depending on
performance, the use of leverage in an investment program may result in higher
(lower) incentive fees for the manager, if leverage magnifies the fund’s value above
(below) the high-watermark. 8 However, based on Dai & Sundaresan (2010), if
managers are willing to decrease the level of leverage (or are forced to do so)
especially during stress periods, this would lower the impact of fees on returns. We
estimate gross returns using the methodology as proposed by Brooks et al. (2007) and
find that the gross-of-fees RLS alpha between the portfolios of low- and high-
leverage classes is slightly higher than the net-of-fees spread alpha. Therefore, the
management and the incentive fees seem to have a larger effect on the low-leverage
classes’ returns.
Theoretical models of Dai & Sundaresan (2010) and Liu & Mello (2011) predict
that hedge funds have incentives to decrease the level of leverage if costs of leverage
are high due to hedge funds’ short positions to funding and redemption options. We
8 The high-water mark means that each investor only pays performance fees when the value of their investment is greater than its previous highest value. Incentive fee is typically subject to “hurdle rate” which is the benchmark return that must be exceeded before the performance-based incentive fees are payable.
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run OLS time series regressions of the RLS returns against several variables that serve
as proxies of costs of leverage (e.g., TED spreads or credit spreads) and show that
these factors have a low explanatory power in return time series of the spread
portfolio. The result suggests that the dynamic adjustment of the leverage conditional
on leverage costs is not driving the difference in performance between low- and high-
leverage classes. The result of the positive and statistically significant RLS alpha
between the portfolios of low- and high-leverage share classes is robust over the 1994
– 2012 sample period.
Our study contributes to Lan et al. (2013). They develop a model where the
manager maximizes the present value of management and incentive fees. By
leveraging alpha-generating strategies, skilled managers add value, but make their
funds riskier. Higher volatility increases the likelihood of poor performance, fund
liquidation, and investors' redemptions. In their world, even a risk-neutral investor
may become risk averse and decrease risk. Theoretical models of Panageas &
Westerfield (2009) and Goetzmann et al. (2003) show that incentive fees can increase
risk taking whereas high-water marks decrease risk taking incentives. Jacobs & Levy
(2013) examine the effects of leverage aversion on portfolio choice. They propose
that portfolio theory’s mean-variance utility function includes a term for leverage
aversion, thereby transforming it into a mean-variance-leverage utility function. They
find that when leverage aversion is included in portfolio optimization, lower mean-
variance-leverage efficient frontiers having less leverage are optimal. Buraschi et al.
(2013) study the link between optimal portfolio choice when the hedge fund manager
is subject to non-linear performance incentives. In their model, the optimal investment
strategy reveals that portfolio leverage depends on the distance from the high-water
mark. The call option (incentive fee) creates an incentive to increasing leverage while
the put option (the investor’s redemption option and prime broker contracts) reduces
this incentive when a high-water mark is above a certain threshold.
We also contribute to the existing literature of hedge fund leverage (Schneeweis
et al. 2005, Liang 1999, McGuire & Tsatsaronis 2008) and show that the average
hedge fund increases the value added though leverage. The main contribution of our
paper is that the average high-leverage class with an adjusted exposure underperforms
the low-leverage counterpart of the same investment program, and therefore, investors
cannot receive full benefits of the levered exposure.
The remainder of the paper is organized as follows. Section 2 provides a
definition of leverage in hedge fund industry. Section 3 shows the data construction.
Section 4 provides empirical results of low- and high-leverage share classes’ average
performance and risk. Section 5 provides the main empirical results of this paper
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including results of relative performance of high-leverage share classes after their
returns are adjusted to the same level with their low-leverage counterparts. Finally,
Section 6 concludes.
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2 Definition of leverage
Hedge fund management companies often have multiple share classes of the same
investment program with various leverage levels. The source of leverage and its
level are likely to change across investment styles. Fixed income arbitrage funds,
for instance, can be more levered than directional traders due to the fact that
arbitrage strategies require leverage in order to exploit small mispricing
(“spreads”) opportunities in financial markets. Therefore, it can be more
straightforward to lever up a directional CTA or a Macro program (with futures,
for instance) than a fixed income arbitrage fund. This section aims to provide a
definition of leverage and give some examples how hedge funds obtain leverage.
Leverage is the link between the underlying inherent risk of an asset and the
actual risk of the investor’s exposure to that asset. The investor’s actual risk has two
components: (1) the market risk (beta) of the asset being purchased; and (2) the
leverage that is applied to the investment. There are three primary leverage types.
First, financial leverage is created through borrowing leverage and/or notional
leverage, and it allows investors to gain risk exposures greater than those that could
be funded only by investing the capital in cash instruments. Second, construction
leverage is created by a combination of securities in a portfolio and depends on the
amount of type of diversification in the portfolio, and the type of hedging applied
(e.g., short positions). Third, instrument leverage reflects to the securities that embed
leverage (e.g., derivative securities). Many hedge funds apply short-term funding
through prime brokers’ borrowing facilities. 9 A purchase of securities – such as
futures, exchange-traded options, and components of structured products that have
leverage already embedded in them – can be done on an exchange or directly from
brokers. Other short-term leverage instruments that hedge funds obtain through
financial intermediaries include repurchase (REPO) and swap agreements. Prime
brokers’ borrowing facilities and term financing (e.g., notes, bonds) are sources of
long-term financing.
If risk is defined by the portfolio’s market risk (beta), all three primary leverage
types can be applied to obtain the same market exposure. There are several reasons
why a hedge fund manager will use leverage in their positions. Directional traders
(e.g., CTA or Macro funds that trade futures and other derivatives) with a high
conviction in trading ideas can enhance returns with leverage. Market neutral and
9 Prime brokers perform a multitude of services including (but not limited to) providing financing for leverage, providing stock loans for shorting, portfolio accounting and performance calculations, and introducing managers to potential investors.
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long/short equity funds may use leverage to reduce the market risk of their portfolios
with short positions. Arbitrage funds (e.g., fixed income) – which combine long/short
positions to fixed income securities, and trade swaps, and other derivatives – may use
leverage to magnify low-risk returns (spreads) that would not be compelling without
leverage. CTA or Macro funds may trade futures contracts due to the better liquidity
and the lower transaction costs of these derivatives contracts if compared to investing
in the referenced assets (e.g., commodity futures). In Ang et al. (2011), the directional
strategies are typically less levered than the arbitrage strategies that have the highest
average gross leverage (some funds have up to 30 gross leverage).
It is challenging to define hedge funds’ leverage across investment styles.
Leverage can be quoted as a ratio of assets to capital or equity (e.g., 4 to 1), as a
percentage (e.g., 400%), or as an incremental percentage (e.g., 300%). A ratio of
assets to capital of 1:1, or a leverage percentage of 100% or less, means that no
leverage is used. Therefore, any incremental percentage greater than 100% means that
leverage is employed.
In a conservative definition of leverage the gross value of assets is divided by the
equity capital. For example, a fund with a $1 million of capital, borrows $250,000 and
invests the full $1.25 million in a portfolio of stocks (i.e. the fund is long $1.25
million). At the same time, let’s assume that a fund sells short $750,000. This refers to
a 200% gross market exposure ($2million/$1million * 100) or a leverage ratio
equaling to 2:1 (i.e. 2X capital to equity). Another fund following a market neutral
strategy with a capital of $1million and is $1million long/$1million short, would have
a 200% gross market exposure but a zero net market exposure. Reporting leverage
varies over strategies. For instance, funds investing primarily in futures (e.g.,
commodities), report a margin-to-equity ratio, which is the amount of cash used to
fund a margin divided by the nominal trading level of the fund. This study has the
caveat that leverage may not be measured in a consistent form across hedge funds,
many of which use different definitions of leverage. We focus on the names of share
classes and use indicators of leverage to make the assumption of investment
programs’ gross market exposure.
Hedge fund managers prefer to make decisions based on optimal leverage as a
function of the investment strategy, the types of securities traded, and the costs of
obtaining leverage. Providers of leverage set maximum constrains on hedge funds’
leverage. Before an investment bank or prime broker will loan money, the manager
has to pledge collaterals to secure the loan, the swap, etc. This collateral is
represented by the securities in their fund or a subset of investments. It is important
for hedge fund managers to negotiate for terms that require a minimum amount of
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collaterals to be posted, flexibility regarding the type of collateral, and minimal
margin requirements for the collateral required. As risk-aversion spreads through the
financial system, investment banks may increase the margin requirements they apply
to the collaterals posted. Effectively, this reduces the leverage that managers can take.
One of the primary factors causing hedge fund failures during stress periods (e.g., the
subprime crisis) has been the demand of the counterparties to return the capital or to
meet the margin calls, which forces managers to liquidate their assets in short order.
Prime brokers have the ability to pull financing in many circumstances, for example,
when performance/NAV triggers are reached. Dai & Sundaresan (2010) show that
hedge funds have short positions to funding and redemption options that are important
limits in hedge funds’ use of leverage.
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3 Data and methodology
3.1 Data of leverage classes
Empirical analysis of hedge fund leverage is challenging due to several reasons. First,
hedge funds may adjust their leverage dynamically based on market conditions, which
is not captured in commercial databases. Instead, they report only the average
leverage of share classes. Second, there is no standard reporting practice of average
leverage in commercial databases. Third, there is little information on how hedge
funds use leverage. For instance, Lipper TASS and Morningstar report binary
variables describing the source of leverage (e.g., margin borrowing, derivatives,
etc.).10 Empirical research that exploits information on time-invariant variables may
suffer from endogeneity problems if the fund’s level of leverage varies with
performance and risk taking. Liang & Qiu (2013) examine 170 monthly snapshots of
the TASS database downloaded from February 2002 to September 2011. They find
that hedge funds rarely change leverage. It might be the case that hedge funds do not
report to a data vendor if they have changed leverage or the data vendor does not
update their leverage fields as frequently as return and asset under management
information. Reporting the average leverage may contain inconsistencies. Some hedge
funds may report the balance sheet leverage which is not adjusted for derivatives
exposure (which is the basic form to measure the level of leverage).11 However, some
hedge funds may report the leverage that is adjusted for derivatives exposure.
Unadjusted balance sheet leverage may understate the true leverage for derivatives-
specialized hedge funds (Breuer 2000).
It is common that multiple database vendors cover the same fund, and that each
database contains multiple share classes for the same investment program. The same
investment program can be included multiple times as a result of varying leverage/fee
levels, different currency/domicile classes, or legal structures. We construct a sample
of share classes that follow the same investment program but apply different levels of
leverage. This allows us to measure the effects of leverage on return and risk as well
as theoretical predictions of leverage aversion.
10 Chen (2011) exploits this information on TASS database and finds that 71% of hedge funds use derivatives. After controlling for fund strategies and characteristics, the paper concludes that on average derivatives users exhibit a lower market and total risk, especially in directional-style funds. 11 Derivative positions (e.g., futures and options) allow the investor to earn the return on the notional amount underlying the contract by committing a small portion of equity in the form of initial margin or option premium payments.
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We identify data of levered share classes from the union of five major databases,
namely, Lipper TASS, Hedge Fund Research, BarclayHedge, EurekaHedge, and
Morningstar. We manually check indicators of leverage (e.g., “1X”, “2X”) from the
names of share classes and find 362 unique share classes for the January 1994 –
December 2012 time period. If the name contains the “2X” indicator, for instance, we
assume that the portfolio has a 2-times levered market exposure. We include all
investment programs that include at least two share classes with different levels of
leverage. Therefore, within each investment program, we measure the performance
difference between duplicate leverage classes. For instance, if a trading program
contains 1X-, 2X-, and 3X-classes, we form three pairs of duplicates: (1) 1X versus
2X; (2) 1X versus 3X; and (3) 2X versus 3X.
We use net-of-fees returns in our baseline analysis and gross-of-fees returns in
robustness checks. Some filters are necessary. First, we prefer share classes with the
longest return time series. Second, we prefer share classes with the largest average
assets under management. Third, in order to prevent double counting of performance-
based fees12, we exclude all funds-of-funds from the baseline analysis. Fourth, we
only include share classes that report returns in the same currency.13 Most of the share
classes have returns in USD. Fifth, we exclude all levered share classes that report the
range of the investment program’s leverage but not the exact level (e.g., “2X-4X”,
“3X-6X”).14 Finally, all share classes are required to have at least 12 months of
reported return history. After imposing all the specified filters, we are left with 141
unique pairs of single-manager share classes. In addition, we identify 35 unique pairs
of fund-of-fund share classes.
Table 1 provides the frequencies of share class pairs using investment strategy
classification (Panel A)15 and the number of unique pairs using the level of leverage
(Panel B). Most of the share class pairs follow CTA (22.7%) or Multi-Strategy
(21.6%) investment styles followed by Fund-of-Funds (19.9%). CTA products take
usually directional bets on the direction of market prices of currencies, commodities,
12 Hedge funds in fund-of-fund portfolios have specific fee structures. A single fund where the fund-of-fund invests may charge “2-20” percent fees (2% management fee and 20% performance-based fee). In addition, the fund-of-fund itself charges fees from its investors. 13 Returns of non-USD share classes are converted into USD using end-of-month spot rates. The exchange rate data is downloaded from Bloomberg. 14 In this case, return adjustment of the high-leverage classes would be difficult. For instance, if the range of leverage is 2X-4X, we could use the arithmetic average ((2+4)/2) =3). However, in construction of spread portfolios, the average leverage (3-times) would be incorrect if the portfolio is only 2-times levered. 15 We follow the strategy classification, which is provided in Appendix 4 of Joenväärä et al. (2014a).
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equities, and bonds in the futures and cash market. Multi-process strategies involve
multiple strategies employed by the funds. For instance, event driven, relative value,
or merger arbitrage may attempt to capture pricing discrepancies (“spreads”) between
assets with higher level of leverage than directional traders. Because directional
traders share a large proportion of the data, we expect that the high-leverage share
classes have (i) higher average return and return variation as well as higher factor
loadings to market risk factors than their low-leverage counterparts. In Table 1, Panel
B shows that multiple leverage-class structures of investment programs are typically
structured in such a way that 1X- and 2X-classes (54%) or 1X- and 3X-classes
(22.7%) are offered for investors. Share classes with more than 3-times leverage
represent a small proportion of the data.
3.2 Equal-weighted portfolios
In this paper, the EW relative leverage spread portfolio between the portfolios of low-
and high-leverage classes is similar to the betting-against-beta portfolio in Frazzini &
Pedersen (2012). At the end of each month, fund share classes are assigned to one of
two portfolios: (1) share classes with low leverage; and (2) share classes with high
leverage. For each of the share class pairs i, which belong to a specific investment
program, we measure the relative leverage spread (RLS) as the return difference
between a low-leverage share class and a high-leverage class as follows:
, ∗ , , (1)
where , is the monthly return of the low-leverage share class and , is the
monthly return of its high-leverage counterpart. In equation (1), and refer
to the leverage levels of the low- and high-leverage share classes. The component
/ adjusts the return of the high-leverage share class to the same level
with the low-leverage share class.
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Table 1. Proportions of share classes by leverage and cross-sectional statistics.
Panel A: Number of share class pairs by strategy.
Strategy Number of Pairs Relative Frequency%
CTA 40 22.7%
Fund-of-Funds 35 19.9%
Global Macro 6 3.4%
Long/Short 13 7.4%
Market Neutral 8 4.5%
Multi-Strategy 38 21.6%
Others 29 16.5%
Relative Value 7 4.0%
Total 176 100%
Panel B: Number of share class pairs.
Leverage Single-Manager Fund-of-Funds All Pairs Relative Frequency%
1X - 1.25X 0 1 1 0.6%
1X - 1.5X 4 0 4 2.3%
1X - 2X 76 19 95 54.0%
1X - 2.5X 5 1 6 3.4%
1X - 3X 34 6 40 22.7%
1X - 4X 3 3 6 3.4%
1X - 5X 2 0 2 1.1%
1X - 6X 1 0 1 0.6%
1.5X - 2X 2 0 2 1.1%
2.X - 3X 7 1 8 4.5%
2.X - 4X 3 2 5 2.8%
2.X - 5X 1 0 1 0.6%
2.X - 7X 1 0 1 0.6%
2.5X - 5X 2 0 2 1.1%
3.X - 4X 0 1 1 0.6%
3.X - 4.5X 0 1 1 0.6%
Total 141 35 176 100.0%
16
Panel C: Cross-sectional statistics of excess returns.
Leverage Mean Median Std Q1 Q3 Min Max
1X and Leveraged (127 pairs)
1X 4.49% 4.01% 1.98% 0.96% 7.70% -26.40% 24.24%
(7.31)
Leveraged 8.90% 7.34% 4.36% 2.55% 15.40% -26.40% 65.64%
(6.59)
Difference (Leveraged – 1X) 4.42% 3.37% 2.86% -0.38% 7.62% -17.76% 50.76%
(4.98)
All share classes (141 pairs)
Low 5.29% 4.2% 2.5% 1.2% 8.5% -26.4% 42.8%
(7.35)
High 10.49% 7.1% 5.5% 3.7% 16.5% -26.4% 116.8%
(6.57)
Difference (High – Low) 5.20% 3.2% 3.6% 0.0% 7.6% -17.8% 77.6%
(5.02)
We construct a sample of investment programs that contain levered share classes from Lipper TASS,
Hedge Fund Research, BarclayHedge, EurekaHedge, and Morningstar databases. We check manually
indicators of the level of leverage from the share classes' name data. If the name data contains, for
instance, an indicator of "2X", we assume 2-times leverage for these portfolios. Using the data of unique
leverage classes, we form groups of share classes that follow the same strategy but use different level of
leverage. Within each group, we form unique pairs of share classes where the first class represents the
low-leverage class and the second class represents the high-leverage class. Panel A shows the
proportion of unique share class pairs by investment strategy and Panel B shows the number of unique
pairs of share classes, which are grouped based on the reported levels of leverage. Panel C provides the
cross-sectional statistics of the average excess returns of the share classes. The first sample contains
the 1X-classes and their leveraged counterparts and the second sample includes all single manager
classes. Fund-of-funds are excluded from both samples. All statistics are annualized and the associated
t-statistics of statistical significance are reported in parentheses. Time period is from January 1994 –
2012.
As an example, if we consider a share class pair i consisting of a 2.5X-class and a
5X-class, the equation (1) becomes:
. , .∗ , , (2)
where monthly returns of the 5X-class are adjusted to the same level with the
2.5X-class. Therefore, the long and short sides of the portfolio have equal
exposures, making the portfolio market neutral. We calculate the return spread for
each of the investment programs and the aggregate spread portfolio that is the
17
equal-weighted and monthly rebalanced average of the individual strategy level
spread returns.
Intuitively, if managers are able to (and willing to) use leverage as their
investment programs suggest, the average performance of the aggregate spread
portfolio should be statistically indistinguishable from zero. According to the
alternative hypothesis, as predicted by the theory of leverage aversion (Frazzini &
Pedersen 2013), the aggregate spread return between low- and high-leverage classes
is positive and statistically significant after returns are adjusted for risk.
18
4 Performance and risk of leveraged share classes, 1994–2012
The idea in this study is to compare performance of the high-leverage share classes to
their low-leverage counterparts. We report statistics separately for the low- and high-
leverage classes as well as for the return difference between these two portfolios. In
this section, we measure the performance of the leveraged share classes without any
adjustment to their returns. Therefore this comparison allows us to examine the effect
of leverage on hedge fund returns and risk. Since the returns of the high-leverage
classes have higher exposure to market risk factors than their low-leverage
counterparts, we expect the high-leverage classes to generate higher returns.
4.1 Cross-sectional statistics
In Panel C of Table 1, we document the cross-sectional statistics of the leverage
classes. We document results for two samples. First, we report the cross-sectional
statistics of the average excess returns for the 1X-classes and their high-leverage
counterparts (127 pairs). Second, we report the cross-sectional statistics of the average
excess returns for all pairs of single-manager share classes (141 pairs). In both
samples, the high-leverage share classes have higher cross-sectional mean of the
average excess returns. In the second sample (141 pairs), the cross-sectional mean of
the average excess returns is 10.49% (t = 6.57) for the high-leverage classes whereas
it is 5.29% (t = 7.35) for the low-leverage classes. The cross-sectional average of the
spread performance is 5.20% (t = 5.02) which is economically and statistically
significant. Both samples provide similar results of the cross-sectional statistics.
Therefore, in rest of the paper, we use the sample that includes all fund class pairs.
4.2 Sorts
In performance evaluation, we follow previous studies and examine hedge funds'
alpha that is the value added of the strategy over passive and "mechanical"
benchmarks. It is important to adjust returns of fund classes to systematic risk in order
to control for the possibility that leverage magnifies the level of market risk. Our main
benchmark model specification for evaluating hedge fund risk-adjusted performance
is the Fung & Hsieh (2004) model. Formally, the model can be shown as:
19
, , , , , 3
where , is the excess return of the investment program (or a fund share class),
measures the abnormal return (FH Alpha), , is the beta risk loading of the factor k
during the time period, , is the factor return at time t, and , is the model's error
term. The seven factors included in the model are: the excess return of the S&P 500
index (SP – RF); the return spread between the Russell 2000 and the S&P 500 index
(RL – SP); the excess return of 10-year U.S. treasuries (TY – RF); the return of
Moody's BAA corporate bonds minus 10-year treasuries (BAA – TY); and the excess
return of the lookback straddles on bonds (PTFSBD); currencies (PTFSFX); and
commodities (PTFSCOM). 16 Returns of hedge funds are often non-normal with
positive or negative skewness and fat tailed distributions (excess kurtosis). Fung &
Hsieh (2001) argue that if hedge fund returns are non-normal, then lookback option-
based trend-following factors increase the model’s ability to explain return variation.
We construct equal-weighted (EW) portfolios of the low- and high-leverage share
classes. We also calculate the spread portfolio that is the return difference between the
high- and low-leverage portfolios. A monthly EW return of a portfolio is simply the
arithmetic average of share classes’ returns in that portfolio. Returns of portfolios are
therefore rebalanced monthly. The estimated FH alpha for the portfolios of low- and
high-leverage share classes implies performance of the average share class in those
portfolios and the alpha of the spread return measures whether the difference between
the two portfolios is economically and statistically significant.
Table 2 reports results of the average performance during the time period of 1994
– 2012 including measures of the average excess return and the standard deviation of
excess return, as well as the estimation results of the Fung & Hsieh (2004) model.
Panel A shows the baseline results. In Panel B, returns are adjusted for backfill-bias
by excluding the first 12 months of the return history from each share class. Results in
Panels A and B reveal that both high-and low-leverage portfolios provide statistically
significant risk-adjusted returns. In Panel A, the high-leverage portfolio provides an
impressive 14.79% alpha and its outperformance with respect to the low-leverage
portfolio is 8.69%. Panel B shows that outperformance of the high-leverage portfolio
16 We download returns of trend-following factors from the web page of David Hsieh (http://people.duke.edu/~dah7/). Fung & Hsieh (2004) model could be augmented using the Pastor & Stambaugh (2003) liquidity factor in order to capture potentially higher liquidity risk exposure in the high-leverage portfolios. The results of this paper are robust to this model specification.
20
is robust to the backfill-adjustment17 which has a small impact on the high- and low-
leverage portfolios (less than 1% per annum). Besides the higher risk-adjusted
performance, the high-leverage portfolio has a significantly higher systematic risk
than the low-leverage portfolio. In Panel A, the factor loadings on S&P 500 index
excess returns, bond, and trend-following factors are about two times higher in the
high-leverage portfolio. This makes sense considering the findings in Table 1 (Panel
B) which shows that a typical share class in the high-leverage portfolio is 2-times
levered. The high- and low-leverage portfolios have significant loadings to the
currency trend-following factor which is a return of the straddle strategy constructed
from various lookback currency options. A high beta to this option-based currency
return suggests that hedge funds take leveraged bets to exploit opportunities in
volatile foreign exchange markets. Despite the higher levels of a total risk and a beta
risk in the high-leverage portfolio, the outperformance of the portfolio is robust across
all performance measures.
Figure 1 plots the time-varying EW average excess returns (Panel A), the
standard deviation of excess returns (Panel B), and the Sharpe ratios (Panel C) of the
low- and high-leverage portfolios. All performance measures are annualized and
estimated in a 36-month rolling window. Consistent with Table 2, the high-leverage
portfolio outperforms consistently over time. However, the magnitude of this
outperformance has become much smaller during and after the recent financial crises.
17 The backfill bias (also known as instant history bias) occurs because hedge funds tend to start reporting performance after a period of a good performance, and that history of a good performance (or a backfill) may be incorporated into the database. Related literature (e.g., Malkiel & Saha 2005, Joenväärä et al. 2014a) shows that backfilled returns are upwardly biased.
21
Ta
ble
2. P
erf
orm
an
ce
of
lev
era
ged
cla
ss
es
.
Pa
ne
l A:
Ba
se
lin
e (
Nu
mb
er
of
sh
are
cla
ss
pa
irs
= 1
41
).
Leve
rage
A
vg.
Exc
ess
Ret
urn
Std
. E
xces
s
Ret
urn
Sha
rpe
Rat
io
FH
Alp
ha
SP
– R
F
RL
– S
P
TY
– R
F
BA
A –
TY
P
TF
SB
D
PT
FS
FX
P
TF
SC
OM
R
²
Low
6.
12%
5.
10%
1.
17
6.10
%
0.04
1 0.
049
0.08
3 0.
014
0.01
0 0.
022
0.01
4 0.
19
(5
.23)
(5
.52)
(1
.80)
(1
.80)
(1
.88)
(0
.28)
(1
.60)
(4
.32)
(1
.92)
Hig
h
14.8
4%
11.2
7%
1.30
14
.79%
0.
090
0.05
9 0.
170
0.05
2 0.
023
0.04
3 0.
033
0.16
(5
.74)
(5
.94)
(1
.76)
(0
.96)
(1
.72)
(0
.45)
(1
.61)
(3
.71)
(2
.05)
Spr
ead
(Hig
h –
Low
) 8.
72%
8.
69%
0.
049
0.01
0 0.
087
0.03
7 0.
013
0.02
1 0.
019
0.12
(5
.6)
(5.6
5)
(1.5
5)
(0.2
6)
(1.4
3)
(0.5
2)
(1.4
5)
(2.8
9)
(1.9
3)
22
Pa
ne
l B
: B
ac
kfi
ll-a
dju
ste
d (
Nu
mb
er
of
sh
are
cla
ss
pair
s =
10
3).
Leve
rage
A
vg.
Exc
ess
Ret
urn
Std
. E
xces
s
Ret
urn
Sha
rpe
Rat
io
FH
Alp
ha
SP
– R
F
RL
– S
P
TY
– R
F
BA
A –
TY
P
TF
SB
D
PT
FS
FX
P
TF
SC
OM
R
²
Low
4.
95%
4.
88%
1.
00
5.16
%
0.00
1 0.
021
0.03
4 0.
063
0.01
5 0.
020
0.01
1 0.
17
(4
.30)
(4
.62)
(0
.04)
(0
.79)
(0
.77)
(1
.26)
(2
.34)
(3
.94)
(1
.55)
Hig
h
13.5
1%
11.6
3%
1.15
14
.15%
0.
014
0.01
2 0.
068
0.12
3 0.
040
0.04
2 0.
021
0.14
(4
.93)
(5
.23)
(0
.26)
(0
.18)
(0
.63)
(1
.01)
(2
.54)
(3
.41)
(1
.22)
Spr
ead
(Hig
h –
Low
) 8.
56%
8.
99%
0.
013
-0.0
09
0.03
4 0.
060
0.02
5 0.
022
0.01
0 0.
11
(5
.00
)
(5
.22
) (0
.38
) (-
0.2
3)
(0.4
9)
(0.7
7)
(2.4
7)
(2.8
1)
(0.9
1)
We c
onst
ruct
tw
o p
ort
folio
s of fu
nd s
hare
cla
sse
s depe
ndin
g o
n the
ir le
vera
ge
. F
or
inst
an
ce,
if a
2X
-cla
ss is
co
mp
are
d t
o a
5X
-cla
ss w
ithin
a s
pe
cific
inve
stm
ent pro
gra
m, th
e 2
X-c
lass
be
longs
to the lo
w-le
vera
ge p
ort
folio
(L
ow
) and t
he 5
X-c
lass
belo
ng
s to
the h
igh-leve
rage p
ort
folio
(H
igh
). T
he
sp
rea
d r
etu
rn
(Hig
h –
Lo
w)
is the
diff
ere
nce
in r
etu
rns
betw
een t
he h
igh-
and lo
w-le
vera
ge p
ort
folio
s. T
his
table
sho
ws
the a
nnualiz
ed a
vera
ge e
xcess
retu
rn (
Avg
. E
xcess
Retu
rn),
the a
nnua
lized s
tan
dard
devi
atio
n o
f exc
ess
retu
rn (
Std
. E
xcess
Retu
rn),
and t
he a
nnualiz
ed F
un
g &
Hsi
eh (
2004)
alp
ha (
FH
Alp
ha)
and it
s
ass
oci
ate
d t
-sta
tistic
in p
are
nth
ese
s. T
he r
isk
loadin
gs
are
as
follo
ws:
exc
ess
retu
rn o
f th
e S
&P
500 in
dex
(SP
− R
F);
retu
rn s
pre
ad b
etw
een t
he R
uss
ell
20
00
ind
ex
an
d t
he
S&
P 5
00
ind
ex
(RL
− S
P);
exc
ess
re
turn
of
10
-ye
ar
Tre
asu
rie
s (T
Y −
RF
); r
etu
rn s
pre
ad
be
twe
en
Mo
od
y’s
BA
A c
orp
ora
te b
on
ds
an
d 1
0-y
ea
r
Tre
asu
rie
s (B
AA
− T
Y);
an
d e
xce
ss r
etu
rns
of
loo
k-b
ack
str
ad
dle
s o
n b
on
ds
(PT
FS
BD
), c
urr
en
cie
s (P
TF
SF
X),
an
d c
om
mo
diti
es
(PT
FS
CO
M),
an
d t
he
last
colu
mn is
th
e R
-sq
uare
d o
f th
e m
odel.
Panel A
show
s th
e b
ase
line r
esu
lts.
In P
anel B
, re
turn
s are
adju
sted for
back
fill-bia
s by
exc
ludin
g the first
12 m
onth
s of
retu
rn h
isto
ry fro
m e
ach
fund s
hare
cla
ss.
23
Fig. 1. Time-varying average performance of leverage classes. Three figures display
the time-varying performance measures of the low- and high-leverage classes.
Returns of the high-leverage share classes are not adjusted at the level of low-
leverage share classes. Reported are effects of leverage on the portfolios' excess
return (Panel A), FH alpha (Panel B), and the return per unit of risk ratio (Sharpe)
(Panel C).
Panel A: Excess returns.
Panel B: Fung & Hsieh (2004) alpha.
0%
5%
10%
15%
20%
25%
30%
35%
Dec-96 May-98 Oct-99 Mar-01 Aug-02 Jan-04 Jun-05 Nov-06 Apr-08 Sep-09 Feb-11 Jul-12
HighLow
0%
5%
10%
15%
20%
25%
30%
35%
40%
Dec-96 May-98 Oct-99 Mar-01 Aug-02 Jan-04 Jun-05 Nov-06 Apr-08 Sep-09 Feb-11 Jul-12
HighLow
24
Panel C: Sharpe ratio.
When the performance measure is a ratio of the average excess return per unit of
risk taken (Sharpe ratio), the high-leverage portfolio performance clearly
converges towards the low-leverage portfolio performance. We calculate the p-
value of the difference (using the procedure of Ledoit & Wolf 2008) in Sharpe
ratios between the low- and high-leverage portfolios and find that the difference
in Sharpe ratios is not statistically significant. Thus, the average performance
remains similar across the low- and high-leverage portfolios when average returns
are measured per unit of risk taken. When comparing share classes with different
levels of leverage, it makes sense to adjust average returns to volatility.
0
0,5
1
1,5
2
2,5
3
Dec-96 May-98 Oct-99 Mar-01 Aug-02 Jan-04 Jun-05 Nov-06 Apr-08 Sep-09 Feb-11 Jul-12
HighLow
25
5 Relative performance of leveraged fund share classes, 1994 – 2012
5.1 Cross-sectional statistics
We measure the difference in returns between low- and high-leverage portfolios as
defined in equation (1) in which the long and short sides of the relative leverage
spread portfolio have equal exposure which makes the spread portfolio market neutral
and balances the risk of the long and short sides. The spread return reflects the
discrepancy between getting market exposure using high-leverage strategies relative
to those of low-leverage strategies. The fundamental question is how to compare the
low- and high-levered returns. One potential measure in this purpose would be the
Treynor ratio statistic which divides excess returns by beta. In this study, we control
the systematic risk of the high-leverage funds by adjusting their returns to the same
level with their low-leverage counterparts.
We provide a case study of a CTA trading program which is managed by the
Ramsey Quantitative Systems, Inc. The program includes one 1X-class and one 2X-
class. Figure 2 (Panel A) shows the cumulative returns of (1) the 1X-class; (2) the 2X-
class with unadjusted returns; and (3) the 2X-class with adjusted returns by
multiplying each monthly return by 0.5. Panel B shows the cumulative RLS returns
measured as a return difference between the 1X-class and the adjusted 2X-class. Also
reported are the annualized arithmetic mean and the annualized standard deviation of
returns. Naturally, the unadjusted 2X-class outperforms the 1X-class (8.1% versus
4.9%) with 2-times higher volatility (6.4%*2 = 12.8%). The unadjusted 2X-class has
a slightly smaller risk/return tradeoff (Sharpe ratios are 0.63 versus 0.77), but it can
add value for the investor due to a higher total return. However, although the 2X-class
has provided two times higher volatility with leverage, the adjusted 2X-class does not
catch up with the performance of the 1X-class. The difference in the average returns
is 90 basis points between the 1X-class and the adjusted 2X-class. Investors may
benefit from the higher expected return of the 2X-class but not that much as expected.
Panel A of Table 3 shows the cross-sectional statistics of the 141 low-and high-
leverage fund share classes as well as their spread performance. The high-leverage
share classes with adjusted returns have a lower cross-sectional mean of the average
excess returns. The cross-sectional mean of the individual strategies' average spread
returns is 0.81% (t = 2.67). This gives us first evidence that the leverage is associated
26
with low returns, as suggested by theory of leverage aversion (Frazzini & Pedersen
2013, Black 1972).
5.2 Sorts
Panels B and C of Table 3 provide further evidence from portfolio sorts. Panel B
shows the baseline results. In Panel C, returns are adjusted for the backfill-bias as in
Table 2. We report results for the EW RLS portfolio and its long and short sides. The
same return and risk measures are reported as in Table 2.
Consistent with theoretical predictions, the RLS portfolio generates statistically
significant average excess returns and FH alphas.18 In Panel B, the average excess
return (FH alpha) of the RLS portfolio is 1.61% (1.63%) with t-statistics above 5.
This result suggests that the return difference between the low-and high-leverage
share classes is statistically significant. The backfill-adjustment drops the average
RLS alpha to 1.07% (t = 3.84) but it is still statistically significant. The return
adjustment of the high-leverage classes shows that the factor loadings are close to the
low-leverage portfolios.
Figure 3 shows the time-varying average excess returns (Panel A) and the FH
alphas (Panel B) for RLS portfolios. As in Figure 1, estimates are measured in a 36-
month rolling window. Results show that the RLS portfolio has a positive
performance over time and during major crisis episodes including those of (1)
September 1998 – November 1998 (the LTCM episode); (2) August 2007 – October
2007 (the Quant crisis); and (3) September 2008 – November 2008 (the Subprime
crisis). During the last period of the sample (2009 – 2012), the RLS portfolio
performance has been moderate. Panel C of Figure 3 reveals that the low-leverage
portfolio outperforms the high-leverage portfolio also in terms of Sharpe ratios. The
performance of the low- and high-leverage portfolios has remained similar during the
years 2003 – 2006 and after 2010.
18 The RLS performance remains robust if additional trend-following factors are included to the Fung & Hsieh (2004) seven-factor factor model.
27
Fig. 2. Performance of individual CTA share classes, June 2003 – June 2010. This
figure shows performance of 1X- and 2X-classes of the CTA strategy managed by
Ramsey Quantitative Systems, Inc. Panel A shows the cumulative returns of (i) the 1X-
class; (ii) the 2X-class; and (iii) the 2X-class after its returns are adjusted at the same
level with the 1X-class. Also included are the average return and the standard
deviation of returns during June 2003 – June 2010. Panel B shows the cumulative
return difference between the 1X-class and the 2X-class with adjusted returns
(Relative leverage spread). The return difference corresponds to the return that
consists of a long position to the low-leverage share class (1X) and short position to
the high-leverage share class (2X) with adjusted returns.
Panel A: Cumulative simple returns of CTA share classes.
Panel B: Cumulative relative leverage spread (RLS).
0%
2%
4%
6%
8%
Jun-03 Apr-04 Feb-05 Dec-05 Oct-06 Sep-07 Jul-08 May-09 Mar-10
-10%
0%
10%
20%
30%
40%
50%
60%
70%
80%
90%
Jun-03 Apr-04 Feb-05 Dec-05 Oct-06 Sep-07 Jul-08 May-09 Mar-10
1X2X (Unadjusted Exposure)2X (Adjusted Exposure)
2X Unadjusted
(Mean=8.1% Std.=12.8%)
1X (Mean=4.9%
Std.=6.4%)
2X Adjusted (Mean=4.0%
Std.=6.4%)
28
Ta
ble
3. R
ela
tiv
e p
erf
orm
an
ce o
f h
igh
-le
ve
rag
e f
un
d c
las
se
s,
19
94
– 2
01
2.
Pa
ne
l A:
Cro
ss-s
ec
tio
nal
sta
tis
tic
s o
f a
ve
rag
e e
xc
es
s r
etu
rns
.
Leve
rage
M
ean
M
edia
n S
td
Q1
Q
3
Min
M
ax
Low
5.
29%
4.
21%
2.
47%
1.
17%
8.
54%
-2
6%
43%
(7
.35)
Hig
h 4.
47%
3.
45%
2.
22%
1.
55%
7.
00%
-1
3%
40%
(6
.91)
Spr
ead
(RLS
) 0.
81%
0.
32%
1.
04%
-0
.22%
2.
08%
-1
8%
17%
Low
– H
igh
(2
.67)
Pa
ne
l B
: B
as
elin
e r
ela
tiv
e l
ev
era
ge
sp
rea
d p
erf
orm
an
ce
(N
um
be
r o
f s
ha
re c
las
s p
air
s =
14
1).
Leve
rage
A
vg.
Exc
ess
Ret
urn
Std
. E
xces
s
Ret
urn
Sha
rpe
Rat
io
FH
Alp
ha
SP
– R
F
RL
– S
P
TY
– R
F
BA
A –
TY
P
TF
SB
D
PT
FS
FX
P
TF
SC
OM
R
²
Low
6.
12%
5.
10%
1.
17
6.10
%
0.04
1 0.
049
0.08
3 0.
014
0.01
0 0.
022
0.01
4 0.
19
(5
.23)
(5
.52)
(1
.80)
(1
.80)
(1
.88)
(0
.28)
(1
.60)
(4
.32)
(1
.92)
Hig
h
4.51
%
4.62
%
0.96
4.
47%
0.
037
0.03
8 0.
076
0.02
1 0.
009
0.02
0 0.
013
0.18
(4
.26)
(4
.44)
(1
.78)
(1
.54)
(1
.90)
(0
.45)
(1
.54)
(4
.23)
(1
.98)
Spr
ead
(RLS
)
1.61
%
1.27
%
1.
63%
0.
004
0.01
1 0.
007
-0.0
07
0.00
1 0.
002
0.00
1 0.
04
Low
– H
igh
(5.5
3)
(5.4
7)
(0.6
9)
(1.4
7)
(0.5
6)
(-0.
47)
(0.7
5)
(1.7
8)
(0.4
6)
29
Pa
ne
l C
: B
ac
kfi
ll-a
dju
ste
d r
ela
tiv
e l
ev
era
ge
sp
rea
d p
erf
orm
an
ce
(N
um
be
r o
f sh
are
cla
ss
pa
irs
= 1
03).
Leve
rage
A
vg.
Exc
ess
Ret
urn
Std
. E
xces
s
Ret
urn
Sha
rpe
Rat
io
FH
Alp
ha
SP
– R
F
RL
– S
P
TY
– R
F
BA
A –
TY
P
TF
SB
D
PT
FS
FX
P
TF
SC
OM
R
²
Low
4.
95%
4.
88%
1.
00
5.16
%
0.00
1 0.
021
0.03
4 0.
063
0.01
5 0.
020
0.01
1 0.
17
(4
.30)
(4
.62)
(0
.04)
(0
.79)
(0
.77)
(1
.26)
(2
.34)
(3
.94)
(1
.55)
Hig
h
3.85
%
4.64
%
0.82
4.
10%
-0
.003
0.
016
0.02
6 0.
068
0.01
5 0.
020
0.01
0 0.
17
(3
.52)
(3
.86)
(-
0.15
) (0
.64)
(0
.60)
(1
.43)
(2
.34)
(4
.09)
(1
.44)
Spr
ead
(RLS
)
1.09
%
1.11
%
1.
07%
0.
004
0.00
5 0.
009
-0.0
05
0.00
1 0.
000
0.00
1 0.
01
Low
– H
igh
(4.1
7)
(3.8
4)
(0.7
3)
(0.7
3)
(0.7
8)
(-0.
38)
(0.4
8)
(0.2
2)
(0.7
2)
We test
sta
tistic
ally
the d
iffere
nce
in r
etu
rns
betw
een lo
w-
and h
igh-le
vera
ge c
lass
es.
Retu
rns
of hig
h-leve
rage c
lass
es
are
ad
just
ed a
t th
e s
am
e le
vel w
ith
low
-leve
rag
e c
lass
es.
The r
ela
tive le
vera
ge s
pre
ad (
RL
S)
retu
rn o
f a s
hare
cla
ss p
air i
is
,∗
, ,
where
is
the r
etu
rn o
f th
e le
vera
ge c
lass
and in
dic
ato
r va
riable
s Lo
w a
nd H
igh r
efe
r to
the le
vel o
f le
vera
ge.
Th
e r
ela
tive le
vera
ge
spre
ad p
ort
folio
is
const
ruct
ed to b
e m
ark
et neutr
al w
ith r
etu
rn o
f each
hig
h-leve
rage c
lass
adju
sted a
t th
e le
vel o
f its
low
-leve
rage c
ounte
rpart
. P
anel A
show
s th
e c
ross
-
sect
ional s
tatis
tics
of th
e a
vera
ge e
xcess
retu
rns
of sh
are
cla
sse
s and P
an
el B
show
s re
sults
of ave
rage p
erf
orm
ance
for
the e
qu
al-w
eig
hte
d p
ort
folio
s. In
Panel C
, re
turn
s a
re a
dju
sted for
back
fill-bia
s by
exc
ludin
g the first
12 m
on
ths
of re
turn
his
tory
fro
m e
ach
share
cla
ss. P
anels
B a
nd
C r
ep
ort
th
e s
am
e r
etu
rn
and r
isk
measu
res
as
Table
2.
Fund-o
f-fu
nds
are
exc
luded f
rom
the s
am
ple
.
30
Fig. 3. Time-varying average relative performance of high-leverage fund share classes.
This figure displays the time-varying performance of the low-leverage and the high-
leverage portfolios as well as their return difference (RLS). The returns of the high-
leverage classes are adjusted at the same level with their low-leverage counterparts.
All performance measures are annualized. Fund-of-funds are excluded.
Panel A: Excess returns.
Panel B: Fung & Hsieh (2004) alphas.
-1%
0%
1%
2%
3%
4%
5%
6%
7%
0%
2%
4%
6%
8%
10%
12%
14%
Dec-96 May-98 Oct-99 Mar-01 Aug-02 Jan-04 Jun-05 Nov-06 Apr-08 Sep-09 Feb-11 Jul-12
Relative Leverage SpreadLow and High Leverage
Relative Leverage Spread (RLS)LowHigh
-1%
0%
1%
2%
3%
4%
5%
0%
2%
4%
6%
8%
10%
12%
14%
16%
18%
Dec-96 May-98 Oct-99 Mar-01 Aug-02 Jan-04 Jun-05 Nov-06 Apr-08 Sep-09 Feb-11 Jul-12
Low and High Leverage Relative Leverage Spread
Relative Leverage Spread (RLS)LowHigh
31
Panel C: Sharpe ratio.
5.3 Robustness
We test the robustness of the RLS performance using a sample that also includes
fund-of-funds for the time period of January 1994 – December 2012. Portfolio sorts in
Table 4 reveal similar RLS performance as in Table 3. Specifically, the RLS alpha is
1.84% with the t-statistic equaling to 6.21. The underperformance of the scaled high-
leverage portfolio is robust to addition of fund-of-funds.
Furthermore, we examine the robustness of the RLS performance during the time
periods of financial distress and major crisis periods, and report results in Table 5.
First, we approximate “flight-to-liquidity” periods as months when (i) the VIX
volatility index has been above its historical median value; (ii) and when the S&P 500
index excess return has been below its historical median. Second, we report the
average returns of RLS portfolios during three important crisis periods: (i) the LTCM
episode; (ii) the Quant crisis; and (iii) the Subprime crisis. During the flight-to-
liquidity periods, the average return of the RLS portfolio is 1.70% (t = 3.04) whereas
it is 1.55% (t = 4.72) after the flight-to-liquidity periods are excluded. During the
financial crisis episodes, we find insignificant average return for the RLS portfolio.
However, the average performance during the financial crisis periods is calculated
using nine return observations referring to small statistical power in analysis. We
conclude that the RLS performance is not driven by specific crisis episodes.
0,0
0,5
1,0
1,5
2,0
2,5
3,0
Dec-96 May-98 Oct-99 Mar-01 Aug-02 Jan-04 Jun-05 Nov-06 Apr-08 Sep-09 Feb-11 Jul-12
LowHigh
32
Ta
ble
4. R
ob
ustn
es
s o
f R
LS
pe
rfo
rman
ce
wit
h f
un
d-o
f-fu
nd
s, 1
99
4 –
20
12
.
Leve
rage
A
vg.
Exc
ess
Ret
urn
Std
. E
xces
s
Ret
urn
Sha
rpe
Rat
io
FH
Alp
ha
SP
– R
F
RL
– S
P
TY
– R
F
BA
A –
TY
P
TF
SB
D
PT
FS
FX
P
TF
SC
OM
R
²
Low
6.
05%
4.
99%
1.
18
5.61
%
0.06
3 0.
045
0.08
2 0.
081
0.00
7 0.
021
0.01
3 0.
17
(
5.28
)
(5
.14)
(2
.82)
(1
.68)
(1
.88)
(1
.60)
(1
.09)
(4
.04)
(1
.78)
Hig
h
4.15
%
4.49
%
0.91
3.
78%
0.
056
0.03
3 0.
069
0.07
8 0.
006
0.01
8 0.
012
0.17
(
4.03
)
(3
.83)
(2
.80)
(1
.37)
(1
.77)
(1
.69)
(1
.15)
(3
.92)
(1
.84)
Spr
ead
(RLS
) 1.
90%
1.
26%
1.84
%
0.00
7 0.
012
0.01
2 0.
004
0.00
0 0.
003
0.00
1 0.
04
Low
– H
igh
(6.
57)
(6.2
1)
(1.0
8)
(1.6
4)
(1.0
5)
(0.2
6)
(0.1
8)
(1.8
6)
(0.4
4)
This
table
sh
ow
s re
sults
of
the a
vera
ge p
erf
orm
ance
of
the R
LS
port
folio
after
fund-o
f-fu
nds
are
incl
uded t
o t
he d
ata
. T
he R
LS
port
folio
is c
onst
ruct
ed a
s in
Table
3. A
ll equal-
weig
hte
d p
ort
folio
s in
clude 1
76 p
airs
of sh
are
cla
sses.
Tim
e p
eriod is
Jan
uary
1994 –
Dece
mber
2012.
33
Table 5. RLS performance during "flight-to-liquidity" periods and financial crisis
episodes.
Average Excess Returns
Flight-to-Liquidity
Periods
Other Periods Financial Crisis Periods Other Periods
Observations 82 146 9 219
Low 4.26% 7.16% 13.20% 5.83%
(2.3) (4.78) (2.03) (4.91)
High 2.56% 5.62% 11.93% 4.21%
(1.59) (4.05) (1.99) (3.92)
Spread (RLS) 1.70% 1.55% 1.24% 1.62%
Low – High (3.04) (4.72) (0.98) (5.44)
This table shows the average excess returns of the equal-weighted RLS factor during the "flight-to-
liquidity" periods and financial crisis episodes. We measure the flight-to-liquidity periods as follows: (i) the
monthly return of the VIX volatility index is above its historical median; and (ii) the S&P 500 monthly
return is below its historical median. We select the following months as financial crisis episodes: (1)
LTCM episode (September 1998 – November 1998); (2) Quant crisis (August 2007 – October 2007); and
(3) Subprime crisis (September 2008 – November 2008). The associated t-statistics of the average
excess returns are reported in parentheses. All fund-of-funds are excluded.
5.4 Fees
Multiple leverage classes within investment programs typically charge the same
management and performance-based fees. Intuitively, depending on performance, the
use of leverage in an investment program may result in higher (lower) incentive fees
for the manager, if leverage magnifies the fund’s value above (below) the high-
watermark. If managers are willing to decrease the level of leverage (or are forced to
do so) especially during stress periods, this would decrease the impact of fees on
returns (Dai & Sundaresan 2010). If the high-leverage classes charge higher incentive
fees than the low-leverage classes, this should be reflected positively to RLS
performance.
We test this prediction with gross returns using the methodology as proposed by
Brooks et al. (2007).19 Portfolio sorts are repeated for share class portfolios with
estimated gross returns and we are left with 134 unique pairs of leverage classes.
Table 6 summarizes the results. Panel A (Panel B) shows the results of sorts for net-
of-fees (gross-of-fees) returns. The RLS portfolio’s gross-of-fees alpha is even larger
19 Their algorithm requires that the management fee and the incentive fees of funds are non-missing in admin modules.
34
than the net-of-fees alpha. In Panel B, the average class in the high-leverage portfolio
has 2.69% lower FH alphas than the average class in the low-leverage portfolio. The
t-statistic (7.5) indicates that the difference in alphas is statistically significant. Since
the gross-of-fees alpha of the RLS portfolio is higher than the net-of-fees alpha, it
indicates that fees have larger impact on returns of low-leverage classes. Thus, these
findings suggest that the asymmetric performance fees do not drive the RLS
performance.
5.5 Time series regressions
Liu & Mello (2011) model theoretically how the fragile nature of the capital structure
in hedge funds combined with imperfect market liquidity hampers funds’ ability to
perform market arbitrage. The fragile equity capital in hedge funds introduces the risk
of coordination among hedge fund investors. The coordination risk arises because
investors suspect that other investors might redeem, and to meet redemptions the fund
may be forced to liquidate positions at a loss. Both the equity and the debt of hedge
funds are fragile since they can be withdrawn on short notice by investors.
The model of Liu & Mello (2011) predicts that the fragile nature of the equity
(and debt) in hedge funds creates an effective market-disciplining mechanism. It
induces hedge funds to behave conservatively, by holding less risky portfolios and
operating with less leverage. Therefore, hedge funds may adjust their level of
leverage based on the costs of leverage.
We test the possibility that the RLS performance is driven by the changes in
borrowing costs. Intuitively, it would be optimal for the manager to adjust the level of
leverage based on the costs of borrowing. For instance, during a financial crisis, when
borrowing costs are likely to be high, hedge funds may decrease their leverage.
We test exposures of the RLS portfolio to various proxies of borrowing costs. We
use the following proxies:
1. Monthly change in the constant maturity 3-month T-bill rate (∆(level));
2. Return to the slope of the yield curve, measured by the yield spread between
the 10-year Treasury rate and the 3-month T-bill rate (∆(Slope))20;
20 Patton and Ramadorai (2013) use ∆(level) and ∆(Slope) as proxies of borrowing costs.
35
Ta
ble
6. G
ros
s p
erf
orm
an
ce
of
RL
S p
ort
foli
o,
19
94
– 2
01
2.
Pa
ne
l A:
Net-
of-
fee
s r
etu
rns
.
Leve
rage
A
vg.
Exc
ess
Ret
urn
Std
. E
xces
s
Ret
urn
Sha
rpe
Rat
io
FH
Alp
haS
P –
RF
R
L –
SP
T
Y –
RF
B
AA
– T
Y
PT
FS
BD
P
TF
SF
X
PT
FS
CO
M
R²
Low
5.
97%
5.
02%
1.
16
5.93
%
0.04
2 0.
047
0.08
1 0.
016
0.01
0 0.
021
0.01
3 0.
18
(5
.18)
(5
.41)
(1
.88)
(1
.72)
(1
.86)
(0
.32)
(1
.67)
(4
.15)
(1
.82)
Hig
h 4.
45%
4.
51%
0.
97
4.39
%
0.04
0 0.
036
0.07
1 0.
023
0.00
9 0.
019
0.01
2 0.
18
(4
.29)
(4
.45)
(1
.96)
(1
.48)
(1
.83)
(0
.51)
(1
.69)
(4
.11)
(1
.89)
Spr
ead
(RLS
) 1.
52%
1.
27%
1.53
%
0.00
3 0.
011
0.00
9 -0
.007
0.
001
0.00
2 0.
001
0.04
Low
– H
igh
(5.2
2)
(5.1
2)
(0.4
4)
(1.4
2)
(0.7
9)
(-0.
50)
(0.5
5)
(1.6
4)
(0.4
2)
Pa
ne
l B
: G
ros
s-o
f-fe
es
re
turn
s.
Leve
rage
A
vg.
Exc
ess
Ret
urn
Std
. E
xces
s
Ret
urn
Sha
rpe
Rat
io
FH
Alp
ha
SP
– R
F
RL
– S
P
TY
– R
F
BA
A –
TY
P
TF
SB
D
PT
FS
FX
P
TF
SC
OM
R
²
Low
10
.22%
5.
95%
1.
68
10.2
1%
0.05
0 0.
055
0.09
2 0.
006
0.01
3 0.
024
0.01
4 0.
17
(7
.48)
(7
.83)
(1
.89)
(1
.69)
(1
.77)
(0
.09)
(1
.72)
(3
.98)
(1
.70)
Hig
h 7.
54%
5.
21%
1.
42
7.52
%
0.04
4 0.
045
0.07
7 0.
016
0.01
1 0.
022
0.01
3 0.
17
(6
.3)
(6.5
8)
(1.8
9)
(1.5
9)
(1.7
0)
(0.3
0)
(1.6
9)
(4.0
4)
(1.7
8)
Spr
ead
(RLS
) 2.
68%
1.
53%
2.69
%
0.00
6 0.
010
0.01
5 -0
.010
0.
002
0.00
3 0.
001
0.04
Low
– H
igh
(7.6
7)
(7.5
0)
(0.8
4)
(1.0
9)
(1.0
5)
(-0.
61)
(0.8
7)
(1.6
1)
(0.4
9)
This
table
sh
ow
s th
e e
qual-w
eig
hte
d R
LS
port
folio
perf
orm
ance
usi
ng g
ross
retu
rns
of le
vera
ge c
lass
es.
Gro
ss r
etu
rns
are
est
ima
ted a
s pro
pose
d b
y B
rooks
et al.
(2007).
We c
onst
ruct
port
folio
s as
in T
able
3.
Pan
el A
show
s re
sults
for
the n
et-
of-
fees
retu
rns
and P
anel B
show
s re
sults
fo
r th
e g
ross
-of-
fee
s re
turn
s. I
n
Panels
A a
nd B
, th
e s
am
ple
incl
udes
134 u
niq
ue p
airs
of
leve
rage c
lass
es.
36
3. The return of Moody’s BAA corporate bonds minus 10-year treasuries (Credit
Spread);
4. TED spread (the 3-month LIBOR rate minus the 3-month T-bill rate) (TED);
5. Value-weighted return of all CRSP firms minus the 1-month T-bill rate (MKT
– RF);
6. Carry trade return of the developed countries' currencies net of transaction
costs (Carry Trade).21
7. VIX straddle return (VIX).
Using the EW portfolios of fund share classes and the proxies of potential costs of
leverage, we estimate the following time series regression using OLS:
α ∑ , , 4
where is the EW portfolio return at time t, is the model’s intercept, is the
sensitivity of the portfolio returns to the proxy k, which is measured at time t ( , , and is the model’s error term.
Table 7 shows the OLS estimation results of the time series regressions for the
monthly EW low- and high-leverage portfolios as well as the spread portfolio
measured as the return difference between the portfolios of low- and high-leverage
share classes. Table reports parameter estimates and their associated t-statistics in
parentheses. In order to examine the effects of leverage on the sensitivities of
portfolio returns to the proxies of borrowing costs, we do not adjust the returns of
high-leverage share classes at the same level with their low-leverage counterparts.
Panels A and B reveal that the portfolios of low- and high-leverage fund share classes
have negative loadings on the ∆(level), ∆(Slope), and the credit spread proxies. In
Panel A, the estimated coefficients of the change in the slope (∆(Slope)) are negative
and statistically significant across model specifications. In the Model 7, for instance,
the estimated loading on the ∆(Slope) is -0.936 (t = -2.50). Therefore, on average, a
one percent increase in the ∆(Slope) has a one percent impact on the EW return of
low-leverage share classes. The portfolio of high-leverage share classes has
considerably higher sensitivities to the proxies of borrowing costs if compared to the
portfolio of low-leverage share classes. For instance, for the portfolio of high-leverage
classes (Panel B), the Model 7 shows that the estimated loading on the ∆(Slope) is -
2.132 (t = -2.57). Panel C, which shows estimation results for the spread returns
between the portfolios of low- and high-leverage classes, confirms that the high-
21 We download the CRSP index return from the Ken French web page. The carry trade factor is from the Hanno Lustig’s web page.
37
leverage portfolio has higher sensitivities to the proxies of borrowings costs.
Nevertheless, the ∆(Slope) is the only proxy that has a statistically significant loading
in regressions. Overall, the ability of the model to explain return behavior of EW
portfolios is negligible. The R² values are small across model specifications.
Table 8 reports the results for the portfolios of low-leverage share classes and
high-leverage share classes, whose returns are adjusted at the same level with their
low-leverage counterparts. Also reported are the estimation results for the RLS factor.
As the Model 7 in Panels A and B suggests, the estimated coefficients of ∆(level)
and ∆(Slope) are negative and statistically significant. The portfolio of high-leverage
share classes has similar estimated coefficients with the portfolio of low-leverage
share classes since the returns of high-leverage classes are adjusted at the same level
with their low-leverage counterparts. The finding is confirmed in Panel C showing
that none of the proxies reveal statistically significant differences between the
portfolios of low- and high-leverage share classes.22 The R² values are small across
model specifications and the ability of time series regressions to explain the return
behavior of EW portfolios seems negligible. In Panel C the estimated intercepts are
positive and statistically significant across model specifications. Thus we conclude
that the result of the positive RLS performance seems not to be explained by the main
proxies of borrowing costs.23 As suggested in Figure 3, the RLS performance is robust
during the study period of 1994 – 2012.
22 This finding remains robust if we use time series regressions having independent variables, which are lagged by one month. 23 In robustness checks which are not reported for reasons of space, we examine whether there is a nonlinear relation between the different proxies of borrowing costs and returns from the RLS factor. We sort the cost proxies into deciles and then examine the spread in the returns on the RLS factor. We find no evidence that the extreme deciles (0 or 10) would provide higher average returns for the RLS factor. The similar result is obtained if the cost proxies are sorted into quintiles.
38
Table 7. Estimation results of time series regressions for equal-weighted portfolios,
1994 – 2012.
Panel A: Low leverage.
Variable [1] [2] [3] [4] [5] [6] [7]
Intercept 0.005 0.005 0.005 0.005 0.005 0.005 0.005
(5.16) (5.09) (5.04) (3.16) (3.05) (2.83) (2.89)
∆(Level) -0.472 -1.1 -1.071 -1.101 -1.117 -1.159 -1.151
(-1.12) (-2.25) (-2.01) (-2.01) (-2.05) (-2.12) (-2.10)
∆(Slope) -0.891 -0.88 -0.873 -0.92 -0.938 -0.936
(-2.47) (-2.37) (-2.34) (-2.46) (-2.51) (-2.50)
Credit Spread -0.007 -0.012 -0.039 -0.053 -0.056
(-0.14) (-0.22) (-0.66) (-0.87) (-0.92)
TED -0.001 -0.001 0.000 0.000
(-0.26) (-0.19) (0.00) (-0.03)
MKT – RF 0.029 0.021 0.011
(1.23) (0.87) (0.35)
Carry Trade 0.045 0.043
(1.23) (1.16)
VIX -0.004
(-0.60)
R² 0.005 0.032 0.032 0.032 0.039 0.045 0.047
Panel B: High leverage (Unadjusted returns).
Variable [1] [2] [3] [4] [5] [6] [7]
Intercept 0.012 0.012 0.012 0.011 0.011 0.01 0.01
(5.69) (5.62) (5.57) (3.04) (2.92) (2.71) (2.73)
∆(Level) -0.444 -1.851 -1.775 -1.708 -1.747 -1.833 -1.823
(-0.47) (-1.71) (-1.5) (-1.41) (-1.45) (-1.52) (-1.50)
∆(Slope) -1.997 -1.967 -1.984 -2.098 -2.134 -2.132
(-2.50) (-2.40) (-2.40) (-2.53) (-2.58) (-2.57)
Credit Spread -0.019 -0.008 -0.074 -0.101 -0.106
(-0.16) (-0.07) (-0.57) (-0.76) (-0.79)
TED 0.002 0.002 0.003 0.003
(0.27) (0.35) (0.52) (0.50)
MKT – RF 0.07 0.054 0.04
(1.34) (1.00) (0.59)
Carry Trade 0.093 0.09
(1.14) (1.09)
VIX -0.006
(-0.37)
R² 0.001 0.028 0.028 0.028 0.036 0.042 0.042
39
Panel C: Spread (High leverage – Low leverage).
Variable [1] [2] [3] [4] [5] [6] [7]
Intercept 0.007 0.007 0.007 0.006 0.006 0.005 0.005
(5.58) (5.50) (5.45) (2.67) (2.56) (2.38) (2.36)
∆(Level) 0.029 -0.751 -0.704 -0.607 -0.63 -0.674 -0.671
(0.05) (-1.15) (-0.99) (-0.83) (-0.86) (-0.92) (-0.92)
∆(Slope) -1.106 -1.088 -1.111 -1.178 -1.196 -1.196
(-2.29) (-2.19) (-2.23) (-2.36) (-2.39) (-2.38)
Credit Spread -0.012 0.004 -0.035 -0.049 -0.05
(-0.17) (0.05) (-0.44) (-0.61) (-0.62)
TED 0.002 0.003 0.003 0.003
(0.65) (0.72) (0.86) (0.85)
MKT – RF 0.041 0.033 0.029
(1.29) (1.00) (0.71)
Carry Trade 0.048 0.047
(0.96) (0.94)
VIX -0.001
(-0.16)
R² 0.000 0.023 0.023 0.025 0.032 0.036 0.036
We test sensitivity of returns of the portfolios of low- and high-leverage fund share classes to changes in
variables that capture the costs of borrowing. We use the following proxies: (1) Monthly change in the constant
maturity 3-month T-bill rate (∆(Level)); (2) The return to the slope of the yield curve, measured by the yield
spread between 10-year Treasury rate and the 3-month T-bill rate (∆(Slope)); (3) The credit spread between
BAA rated bonds and the 10-year Treasury rate (Credit Spread); (4) TED spread (the 3-month LIBOR rate
minus the 3-month T-bill rate) (TED); (5) Value-weighted return of all CRSP firms minus the 1-month Treasury
bill rate (MKT – RF); (6) Carry trade return of the developed countries' currencies net of transaction costs
(Carry Trade); and (7) VIX returns (VIX). We run a time series regression for the portfolios of low-leverage
(Panel A) and high-leverage (Panel B) share classes against the proxies of borrowing costs using OLS. We
also run a time series regression for the spread returns measured as the return difference between the
portfolios of low- and high-leverage share classes. All independent variables are contemporaneously
measured. The t-statistics of estimated coefficients are reported in parentheses.
40
Table 8. Estimation results of time series regressions for equal-weighted RLS
portfolio, 1994 – 2012.
Panel A: Low leverage.
Variable [1] [2] [3] [4] [5] [6] [7]
Intercept 0.005 0.005 0.005 0.005 0.005 0.005 0.005
(5.16) (5.09) (5.04) (3.16) (3.05) (2.83) (2.89)
∆(Level) -0.472 -1.100 -1.071 -1.101 -1.117 -1.159 -1.151
(-1.12) (-2.25) (-2.01) (-2.01) (-2.05) (-2.12) (-2.10)
∆(Slope) -0.891 -0.880 -0.873 -0.920 -0.938 -0.936
(-2.47) (-2.37) (-2.34) (-2.46) (-2.51) (-2.50)
Credit Spread -0.007 -0.012 -0.039 -0.053 -0.056
(-0.14) (-0.22) (-0.66) (-0.87) (-0.92)
TED -0.001 -0.001 0.000 0.000
(-0.26) (-0.19) (0.00) (-0.03)
MKT – RF 0.029 0.021 0.011
(1.23) (0.87) (0.35)
Carry Trade 0.045 0.043
(1.23) (1.16)
VIX -0.004
(-0.60)
R² 0.005 0.032 0.032 0.032 0.039 0.045 0.047
Panel B: High leverage (Adjusted returns).
Variable [1] [2] [3] [4] [5] [6] [7]
Intercept 0.004 0.004 0.004 0.004 0.004 0.004 0.004
(4.20) (4.11) (4.06) (2.61) (2.50) (2.28) (2.35)
∆(Level) -0.369 -0.933 -0.925 -0.954 -0.969 -1.007 -1.000
(-0.96) (-2.10) (-1.91) (-1.93) (-1.96) (-2.03) (-2.01)
∆(Slope) -0.801 -0.798 -0.791 -0.835 -0.851 -0.849
(-2.45) (-2.37) (-2.34) (-2.46) (-2.51) (-2.50)
Credit Spread -0.002 -0.007 -0.032 -0.044 -0.047
(-0.04) (-0.13) (-0.60) (-0.81) (-0.86)
TED -0.001 -0.001 0.000 0.000
(-0.29) (-0.21) (-0.02) (-0.05)
MKT – RF 0.027 0.020 0.010
(1.25) (0.89) (0.35)
Carry Trade 0.041 0.039
(1.23) (1.16)
VIX -0.004
(-0.64)
R² 0.004 0.030 0.030 0.030 0.037 0.044 0.045
41
Panel C: Relative leverage spread (RLS).
Variable [1] [2] [3] [4] [5] [6] [7]
Intercept 0.001 0.001 0.001 0.001 0.001 0.001 0.001
(5.47) (5.41) (5.39) (3.18) (3.12) (3.01) (2.98)
∆(Level) -0.103 -0.167 -0.146 -0.147 -0.148 -0.152 -0.152
(-0.98) (-1.36) (-1.09) (-1.07) (-1.08) (-1.10) (-1.09)
∆(Slope) -0.090 -0.082 -0.082 -0.085 -0.087 -0.087
(-0.99) (-0.88) (-0.87) (-0.91) (-0.92) (-0.92)
Credit Spread -0.005 -0.005 -0.007 -0.009 -0.009
(-0.39) (-0.37) (-0.49) (-0.56) (-0.56)
TED 0.000 0.000 0.000 0.000
(-0.02) (0.00) (0.07) (0.06)
MKT – RF 0.002 0.002 0.001
(0.39) (0.26) (0.16)
Carry Trade 0.004 0.004
(0.44) (0.43)
VIX 0.000
(-0.08)
R² 0.004 0.009 0.009 0.009 0.010 0.011 0.011
We test the sensitivity of RLS performance to changes in variables that capture the costs of borrowing. We
use the same independent variables as in Table 7. We run a time series regression for the portfolios of low-
leverage share classes (Panel A) and high-leverage share classes (Panel B) against the proxies of borrowing
costs using OLS. The returns of high-leverage share classes are adjusted to the same level with their low-
leverage counterparts. Panel C reports estimation results for the RLS portfolio. All independent variables are
contemporaneously measured. The t-statistics of estimated coefficients are reported in parentheses.
42
6 Conclusions
This study builds on the theoretical work of leverage aversion and margin constraints.
Using a hand-collected data on levered fund share classes from the union of major
commercial databases, we document that the share classes with high leverage exhibit
higher risk-adjusted returns, a systematic risk, and higher volatility than their low-
leverage counterparts. We find that the average low- and high-leverage share class
generates an economically and statistically significant FH alpha, which is in line with
previous literature suggesting that hedge funds add value for their investors.
The main finding of this study is that the average high-leverage share class
underperforms its low-leverage counterpart for the same investment program after
their returns are appropriately adjusted to the same level. More specifically, a relative
leverage spread (RLS) portfolio with long low-leverage share classes and short high-
leverage share classes generates significant risk-adjusted performance. During the
time period January 1994 – December 2012, the RLS portfolio of single manager
share classes generates a 1.63% FH alpha which is statistically significant. The result
is robust to the inclusion of fund-of-funds, sub periods, and gross returns. We also
document that the general proxies of the cost of leverage do not have any significant
explanatory power in explaining RLS returns.
The results of this study mirror the theoretical predictions of Frazzini & Pedersen
(2013) and Dai & Sundaresan (2010) suggesting that leverage aversion has an impact
on hedge fund performance. Therefore, investors may receive higher total returns by
investing in share classes with high-leverage. However, the RLS performance
indicates that investors do not receive benefits from high leverage as much as
suggested.
Our results imply that buying hedge funds with high leverage embedded in their
strategies increases investors' market exposure and value added without violating their
leverage constraints. Pension funds, for instance, which can be leverage-constrained
investors, can exploit leverage, which is embedded in fund share classes. Careful
monitoring of the hedge funds’ level of leverage and their exposures to market risk
factors is expected to add value.
This study examines the theoretical predictions of leverage aversion by exploiting
the monthly returns of fund share classes with various levels of leverage. The
examination of these theoretical predictions using the security-level data of the
management companies’ use of derivatives would be an interesting extension to this
study.
43
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