CORRECTION TO BLACK-SCHOLES FORMULA DUE TO
FRACTIONAL STOCHASTIC VOLATILITY
arXiv:1509.01175v2 [q-fin.MF] 19 Mar 2017
JOSSELIN GARNIER∗ AND KNUT SØLNA†
Abstract. Empirical studies show that the volatility may exhibit correlations that decay as a
fractional power of the time offset. The paper presents a rigorous analysis for the case when the
stationary stochastic volatility model is constructed in terms of a fractional Ornstein Uhlenbeck
process to have such correlations. It is shown how the associated implied volatility has a term
structure that is a function of maturity to a fractional power.
Key words. Stochastic volatility, implied volatility, fractional Brownian motion, long-range
dependence.
AMS subject classifications. 91G80, 60H10, 60G22, 60K37.
1. Introduction. Our aim in this paper is to provide a framework for analysis of
stochastic volatility problems in the context when the volatility process possesses correlations that decays like a power law. We will both consider the case of “long-range”
processes where the consecutive increments of the process are positively correlated,
corresponding to the so called Hurst coefficient H > 1/2, as well as the case with
“short-range” processes with consecutive increments being negatively correlated with
H < 1/2. Replacing the constant volatility of the Black-Scholes model with a random
process gives price modifications in financial contracts. It is important to understand
the qualitative behavior of such price modifications for a (class of) stochastic volatility
models since this can be used for calibration purposes. Typically the price modifications are parameterized by the implied volatility relative to the Black-Scholes model
[27, 42]. For illustration we consider here European option pricing and then the implied volatility depends on the moneyness, the ratio between the strike price and the
current price, moreover, the time to maturity. The term and moneyness structure
of the implied volatility can be calibrated with respect to liquid contracts and then
used for pricing of related but less liquid contracts. Much of the work on stochastic
volatility models have focussed on situations when the volatility process is a Markov
process, commonly some sort of a jump diffusion process. However, a number of
empirical studies suggest that the volatility process possesses long- and short-range
dependence, that is the correlation function of the volatility process has decay that is
a fractional power of the time offset. This is the class of volatility models we consider
here. We find that such correlations indeed reflect themself in an implied volatility
fractional term structure. An important aspect of the modeling is also the presence of
correlation between the volatility shocks and the shocks (driving Brownian motion) of
the underlying, this “leverage effect” influences the implied volatility in an important
way and we shall include it below. The leverage effect is well motivated from the
modeling viewpoint and important to incorporate to fit observed implied volatilities,
albeit a challenging quantity to estimate [2]. Evidence of leverage and persistence
or long-range dependencies have been found by considering high-frequency data and
incorporated in discrete time series models [8, 20, 43].
Here we model in terms of a continuous time stochastic volatility model that is
∗ Laboratoire de Probabilités et Modèles Aléatoires & Laboratoire Jacques-Louis Lions, Université
Paris Diderot, 75205 Paris Cedex 13, France garnier@math.univ-paris-diderot.fr
† Department of Mathematics, University of California, Irvine CA 92697 ksolna@math.uci.edu
1
a smooth function of a Gaussian process. We use a martingale method approach
which exploits the fact that the discounted price process is a (local) martingale. We
model the fractional stochastic volatility (fSV) as a smooth function of a fractional
Ornstein-Uhlenbeck (fOU) process. We moreover assume that the fSV model has
relatively small fluctuations, of magnitude δ ≪ 1 and we derive the associated leading
order expression for implied volatility with respect to this parameter via an asymptotic
analysis. This gives a parsimonious parameterization of the implied volatility which
may be exploited for robust calibration. The fOU process is a classic model for
a stationary process with a fractional correlation structure. This process can be
expressed in terms of an integral of a fractional Brownian motion (fBm) process.
The distribution of a fBm process is characterized in terms of the Hurst exponent
H ∈ (0, 1). The fBm process is locally Hölder continuous of exponent α for all α < H
and this property is inherited by the fOU process. The fBm process, WtH , is also
self-similar in that
H
dist.
Wαt , t ∈ R = αH WtH , t ∈ R for all α > 0.
(1.1)
The self-similarity property is inherited approximately by the fOU process on scales
smaller than the mean reversion time of the fOU process that we will denote by 1/a
below. In this sense we may refer to the fOU process as a multiscale process on
relatively short scales.
The case with H ∈ (0, 1/2) gives a fOU process that is a so-called “short-range”
dependent process that is rough on short scales and whose correlations for small time
offsets decay faster than the linear decay associated with a Markov process. In fact the
decay is as the offset to the fractional power 2H. In this regime consecutive increments
of the fBm process are negatively correlated giving a rough process also referred to
as an anti-persistent process. The enhanced negative correlation with smaller Hurst
exponent gives a relatively rougher process.
The case with H ∈ (1/2, 1) gives a fOU process that is a so-called “long-range”
dependent process whose correlations for large time offsets decays as the offset to the
fractional power 2(H − 1). It follows that the correlation function of the fOU process
is not integrable. This regime corresponds to a persistent process where consecutive increments of the fBm are positively correlated. The relatively stronger positive
correlation for the consecutive increments of the associated fBm process with increasing H values gives a relatively smoother process whose correlations decay relatively
slowly. For more details regarding the fBm and fOU processes we refer repectively to
[7, 17, 18, 37] and [10, 35].
In order to simplify notation and interpretation of the results we present them in
the context of the fractional OU process. However, as we show in Appendix B, the
results readily generalize to the case with general Gaussian processes with short- and
long-range dependence.
A large number of recent papers have considered modeling of volatility in terms of
processes with short- and long-range dependence. In [13] the authors consider a long
memory extension of the Heston [34] option pricing model, a fractionally integrated
square root process, a generalization of the early work in [14]. They make use of
the analytical tractability of this model, in fact a fractionally integrated version of
a Markovian affine diffusion, with affine diffusions considered in [19]. The emphasis
is on the long-range dependent case (H > 1/2) and long time to maturity. The authors focus on the conditional expectation of the integrated square volatility and show
the fractional decay of this, moreover, they discuss estimation schemes for model parameters based on discrete observations. In the Markovian case the mean integrated
2
square volatility would exponentially fast approach its mean value and flatten the
implied volatility term structure. They remark that long-range dependence provides
an explanation for observations of non-flat term structure in the regime of large maturities since the long-range dependence may make the implied volatility smile strongly
maturity-dependent in this regime, while also producing consistent smiles for short
maturities. The model presented in [13] was recently revisited in [31] where short and
long maturity asymptotics are analyzed using large deviations principles.
The concept of RFSV, Rough Fractional Stochastic Volatility, is put forward in
[5, 30]. Here a model with log-volatility modeled by a fBm is motivated by analysis
of market data, which they state provide strong support for a value for the Hurst
exponent H around 0.1. As explained above small values for H correspond to very
rough processes. It is remarked that such a process can be motivated by modeling of
order flow using Hawkes processes. The authors discuss issues related to change from
physical to pricing measure and use simulated prices to fit well the implied volatility
surface in the case of SPX with few parameters. They argue that the fractional model
generates strong skews or “smiles” in the implied volatility even for very short time
to maturity so that this modeling provides an alternative to using jumps to model
such an effect. The form of the implied volatility surface and the structure of the
returns have been used to argue that the asset price should be a jump process [1, 9].
Indeed models with jumps may be used as an alternative approach to capture smile
dynamics to the fractional approach considered here and recent contributions consider
models driven by Lévy processes both for volatility models [21, 40] and directly for
price models [4].
A variant of the model in [30] is considered in [39] where the log-volatility is
modeled as a fractional noise, with fractional noise being the increment process of a
fBm for a certain increment length. The authors discuss the well-posedness of this
model from the financial perspective and in doing so make use of a truncated version
of the integral representation of the fBm. In [38] this model is supported by data
analysis and motivated by an agent-based interpretation.
In [11, 12] the authors consider the situation when the volatility is modeled as a
function of a fOU process whose shocks are independent from those of the underlying.
Their focus is on a tree-based method for computing prices, estimation schemes for
model parameters, and a particle filtering technique for the unobserved volatility given
discrete observations. They consider some real data examples and find estimated
values for the Hurst exponent which is larger than 1/2, in particular in a period after
a market crash. In [32] small maturity asymptotic results are presented for this model.
Among the many papers considering short maturity asymptotics, in the early
paper [3] Alós et al. use Malliavin calculus to get expressions for the implied volatility
in the regime of small maturity. They find that the implied volatility diverges in the
short-range dependent case and flattens in the long-range dependent case in the limit
of small maturity. These results are consistent with what we present below. The
modeling in [3] differs from the modeling below in that the authors consider volatility
fluctuations at the order one level while below the fluctuations are relatively small,
however, we consider any time to maturity.
Fukasawa [28] discusses the case with small volatility fluctuations and short- and
long-range dependence impact on the implied volatility as an application of the general
theory he sets forth. He uses a non-stationary “planar” fBm as the volatility factor
so that the leading implied volatility surface is identified conditioned on the present
value of the implied volatility factor only, while below with a stationary model the
3
surface depends on the path of the volatility factor until the present, reflecting the
non-Markovian nature of fBm. In [29] Fukasawa discusses the case of short-range
dependent processes and short time to maturity and a framework for expansion of the
implied volatility surface. He uses a representation of fBm due to Muralev [41]. He
also considers local stochastic volatility models and find that these are not consistent
with power laws in this regime.
As a further generalization relative to a fractional Brownian motion based model
the case of multi fractional Brownian motion based models is considered in [16]. This
allows for a non-stationary local regularity or a time dependent Hurst exponent and
then the implied volatility depends on weighted averages of the local Hurst exponent.
In [23] Forde and Zhang use large deviation principles to compute the short maturity asymptotic form of the implied volatility. They consider the correlated case
with leverage and obtain results that are consistent with those in [3]. They consider
a stochastic volatility model based on fBm and also more general ones where the
volatility process is driven by fBms and which is analyzed using rough path theory.
They also consider large time asymptotics for some fractional processes.
Indeed, a number of recent papers have considered small maturity asymptotics
for implied volatility in the context of mixing, short- or long-range processes. Many of
these use large deviation principles or heat kernel expansions [6, 23, 33], while another
approach is to consider the regime around the money [3, 29, 40]. Recent works deal
also with the regime of large strikes and derive bounds on the implied volatility [36].
Here we take another approach by considering a perturbation situation so that the
implied volatility can be expanded around an effective volatility [27], also for large
times to maturity. We model the volatility as a stationary process, a continuous
time stationary short- or long-range dependent stochastic volatility process, with a
view toward constructing a time consistent scheme. We use an approach based on
the martingale method which is adapted to the fact that the volatility process is
not a Markov process. We explicitly take into account the effects of correlation in
between volatility shocks and shocks in the underlying, the leverage effect, and its
form in short- and long-range dependent cases. We obtain expressions for the implied
volatility for all times to maturity and also for log-moneyness of order one. Explicitly,
we model the volatility as
σt = σ̄ + F (δZtH ),
(1.2)
for ZtH the fOU process that we discuss in more detail in Section 2.2. The function
F is assumed to be one-to-one, smooth, bounded from below by a constant larger
than −σ̄, with bounded derivatives, and such that F (0) = 0 and F ′ (0) = 1.
It
follows that the volatility process inherits (qualitatively) the correlation properties of
the fBm process. Indeed, we have
σt = σ̄ + F (δZtH ) = σ̄ + δZtH + δ 2 hδ (ZtH )
(1.3)
where hδ (y) = (F (δy) − δy)/δ 2 can be bounded uniformly in δ by:
|hδ (y)| ≤ kF ′′ k∞ y 2 .
(1.4)
Note that throughout the paper we will be working with non-dimensionalized quantities. Specifically, if t′ represents dimensionalized time say in units of “trading year”
and T ′ is a typical time horizon being for instance a typical maturity time in years
then t is the non-dimensionalized time:
t′
(1.5)
t = ′.
T
4
The main result is then the associated form for the implied volatility, see Equations (5.1), (5.3) and (5.4) below, we summarize the result next. The implied volatility
is here the volatility value that needs to be used in the constant volatility Black-Scholes
European option pricing formula in order to replicate the asymptotic fSV option price,
it is, up to terms of order δ 2 :
h
i 12
h 1 Z T
log(K/Xt ) i
,
(1.6)
It = E
σs2 ds|Ft + A(T − t) 1 +
T −t t
(T − t)/τ̄
for
1
A(τ ) =
δρσ̄τ H+ 2 n
1−
2Γ(H + 52 )
Z
aτ
0
e−v 1 −
v H+ 32 o
dv ,
aτ
(1.7)
where 1/a is the mean reversion time of the fOU process and τ̄ = 2/σ̄ 2 a characteristic
diffusion time for the underlying. Furthermore, Xt is the underlying price process with
evolution as in (3.1) and Ft its associated filtration. Moreover, ρ is the correlation
in between the Brownian motions driving respectively the volatility process and the
underlying price process, K is the strike price so that K/X is the moneyness, and
finally τ = T − t is time to maturity. The first term in the implied volatility is the
expected effective volatility over the remaining time period of the option conditioned
on the knowledge at time t, note that this term is random. The second term is a
leverage term which is present in the case that the underlying and the volatility have
correlated evolutions so that ρ is non-zero. Note that ρ is commonly assumed to be
negative. The log-moneyness term becomes relatively more important as the time to
maturity becomes small relative to the characteristic diffusion time.
In the short and long time to maturity regimes we then have for the leverage
term:
h
i
1
1
+H
h
+ (τ /τ̄ )− 2 +H log(K/Xt )
for aτ ≪ 1,
log(K/Xt ) i ash (τ /τ̄ ) 2
i
=
A(τ ) 1 +
1
3
−
+H
−
+H
al (τ /τ̄ ) 2
τ /τ̄
+ (τ /τ̄ ) 2 log(K/Xt )
for aτ ≫ 1 ,
(1.8)
with
δρτ̄ H−1
al = √
.
2aΓ(H + 23 )
δρτ̄ H
as = √
,
2Γ(H + 52 )
We moreover have for the predicted effective volatility term:
i 21
h 1 Z T
σt for aτ ≪ 1,
2
σs ds|Ft =
σt,T ≡ E
σ̄
for aτ ≫ 1.
T −t t
(1.9)
(1.10)
It is important to note that we only assume τ = T − t > 0 so that in fact the implied
volatility for small times to maturity may be very large for short-range dependent
processes. This reflects the fact that for short-range dependent processes the volatility
path is rough and may have a significant impact beyond the current predicted effective
volatility level. However, when used in the standard Black-Scholes pricing formula
the implied volatility indeed gives a pricing correction that is O(δ) for any τ > 0. We
also note that in the long maturity regime the implied volatility level may diverge for
long-range dependent processes reflecting the fact that long-range dependence gives
5
strong temporal coherence and therefore relatively large corrections to the predicted
current effective volatility.
Note next that the calibration of the leverage component of the implied volatility
in the general case in (1.6) involves estimation of the group market parameters:
σ̄,
H,
(δρ),
a,
(1.11)
from observed implied volatility data. In order to fully identify the model at the
current time t we need moreover to estimate the current predicted effective volatility
over a time to maturity horizon, that is, σt,t+τ for 0 ≤ τ ≤ Tmax − t.
It is important to note that in our framework the market parameters are from
the theoretical point of view independent of the current time t. Thus, in order to
calibrate the model with data over a current time epoch t1 ≤ t ≤ t2 one may use all
the implied volatility recording in a joint fitting procedure.
We remark that our results would be modified under the presence of general interest rates and market price of risk factors that we do not consider here. We also remark
that identifying a “smile” shape, that is a more general function in log-moneyness,
would require a higher-order approximation of implied volatility [26]. Finally, observe
that the case H = 1/2 corresponds neither to a short-range dependent process nor a
long-range dependent process, but the standard case of an Ornstein-Uhlenbeck process and a stochastic volatility that is a Markovian process with correlations decaying
exponentially fast [27].
The framework we have presented is general and can be used for processes for
which we can identify the key quantities of interest below. We discuss one important
special case corresponding to a slow fOU process. In this case we model the volatility
in terms of the “slow” fOU process Z δ,H :
Z t
δ,H
H
Zt = δ
e−δa(t−s) dWsH ,
(1.12)
−∞
whose natural time scale is 1/δ and whose variance is order one and given by σou
defined by (2.5) below, independently of δ. Then the volatility is
σt = F (Ztδ,H ),
(1.13)
where F is a smooth, positive-valued function, bounded away from zero, with bounded
derivatives. We introduce the two parameters
σ0 = F (Z0δ,H ),
p0 = F ′ (Z0δ,H ),
(1.14)
that is, the local level and rate of change of the volatility. In this case the implied
volatility is given by:
h 1 Z T
i
i 12
1
1
δ H p0 ρτ0H h
2 +H + (τ /τ )− 2 +H log(K/X ) ,
It = E
(τ
/τ
)
σs2 ds|Ft + √
0
0
t
T −t t
2Γ(H + 25 )
(1.15)
for τ0 = 2/σ02 . Thus, the slow fractional volatility factor yields an implied volatility
that corresponds to the one of the fractional model in (1.2) in the regime of small
maturity, as given in (1.8). In the special case that H = 1/2 the volatility process
becomes a standard Ornstein-Uhlenbeck process and is in the class of slow processes
considered in [27] and indeed the implied volatility in (1.15) can then be show to be
exactly of the form discussed for the slow correction in [27] (Chapter 5).
6
The outline of the paper is as follows. First in Section 2 we introduce the details
of the ingredients of the fSV model. In Section 3 we derive the main result of the
paper, the leading order expression for the price in the situation with a fSV. The
derivation is based on a contract with a smooth payoff function while the European
payoff function has a kink singularity and we generalize the result to this situation
in Section 4. Then in Section 5 we derive the expression for the implied volatility
and how the fractional character of the volatility affects this. We connect to the slow
time volatility model in Section 6 and present some concluding remarks in Section 7.
In Appendix A we characterize some quantities of interest and associated technical
lemmas that are being used in the price derivation in Section 3.
2. The fractional stochastic volatility model. We describe in more detail
the fBm and fOU processes that are used in the fSV construction (1.2).
2.1. Fractional Brownian motion and its moving-average stochastic integral representation. A fractional Brownian motion (fBm) is a zero-mean Gaussian process (WtH )t∈R with the covariance
E[WtH WsH ] =
2
σH
|t|2H + |s|2H − |t − s|2H ,
2
(2.1)
where σH is a positive constant.
We use the following moving-average stochastic integral representation of the fBm
[37]:
Z
1
H− 1
H− 1
H
(2.2)
Wt =
(t − s)+ 2 − (−s)+ 2 dWs ,
1
Γ(H + 2 ) R
where (Wt )t∈R is a standard Brownian motion over R. In this model (WtH )t∈R is a
zero-mean Gaussian process with the covariance (2.1) where
hZ ∞
1 i
1
H− 21 2
H− 12
2
ds
+
−
s
(1
+
s)
σH
=
2H
Γ(H + 12 )2 0
1
=
.
(2.3)
Γ(2H + 1) sin(πH)
2.2. The fractional Ornstein-Uhlenbeck process. We then introduce the
fractional Ornstein-Uhlenbeck process (fOU) as
ZtH =
Z
t
−∞
e−a(t−s) dWsH = WtH − a
Z
t
−∞
e−a(t−s) WsH ds.
(2.4)
It is a zero-mean, stationary Gaussian process, with variance
2
σou
= E[(ZtH )2 ] =
1 −2H
2
a
Γ(2H + 1)σH
,
2
(2.5)
and covariance:
h1 Z
i
1
e−|v| |as + v|2H dv − |as|2H
Γ(2H + 1) 2 R
Z
2
sin(πH) ∞
x1−2H
2
= σou
dx.
cos(asx)
π
1 + x2
0
H
2
E[ZtH Zt+s
] = σou
7
(2.6)
Note that it is not a martingale, neither a Markov process.
Substituting (2.2) into the second representation in Eq. (2.4) gives in view of
stochastic Fubini the moving-average integral representation of the fOU:
Z t
ZtH =
K(t − s)dWs ,
(2.7)
−∞
where
h
1
1
tH− 2 − a
1
Γ(H + 2 )
K(t) =
Z
0
t
i
1
(t − s)H− 2 e−as ds .
(2.8)
The properties of the kernel K are the following ones:
R∞
2
- K is nonnegative-valued, K ∈ L2 (0, ∞) for any H ∈ (0, 1) with 0 K2 (u)du = σou
,
and K ∈ L1 (0, ∞) for any H ∈ (0, 1/2).
- For small times at ≪ 1:
1
H− 12
H− 21
K(t) =
(at)
.
(2.9)
+
o
(at)
1
Γ(H + 21 )aH− 2
- For large times at ≫ 1:
K(t) =
1
Γ(H − 21 )a
H− 23
H− 32
.
+
o
(at)
(at)
H− 1
(2.10)
2
For H ∈ (0, 1/2) the fOU process possesses short-range correlation properties:
H
2
E[ZtH Zt+s
] = σou
1−
1
(as)2H + o (as)2H ,
Γ(2H + 1)
as ≪ 1.
(2.11)
as ≫ 1.
(2.12)
For H ∈ (1/2, 1) it possesses long-range correlation properties:
H
2
E[ZtH Zt+s
] = σou
1
(as)2H−2 + o (as)2H−2 ,
Γ(2H − 1)
The expansion (2.12) is valid for any H ∈ (0, 1/2) ∪ (1/2, 1) and for H ∈ (1/2, 1) it
shows that the correlation function is not integrable at infinity. This is in contrast to
the case of short-range dependent processes and also to Markov processes for which
the correlation function is integrable.
3. The option price. The price of the risky asset follows the stochastic differential equation:
dXt = σt Xt dWt∗ ,
(3.1)
σt = σ̄ + F (δZtH ),
(3.2)
where the stochastic volatility is
ZtH has been introduced in the previous section and is adapted to the Brownian
motion Wt , and Wt∗ is a Brownian motion that is correlated to the stochastic volatility
through
p
(3.3)
Wt∗ = ρWt + 1 − ρ2 Bt ,
8
where the Brownian motion Bt is independent of Wt . We remark that the main aspect
of the model whose consequences we want to analyze here are the short- respectively
long-range properties of the correlation function in Eqs. (2.11) and (2.12) under the
presence of leverage as in Eq. (3.3). We will find that this has a dramatic effect on
the asymptotic prices and the associated implied volatility.
The function F is assumed to be one-to-one, smooth, bounded from below by a
constant larger than −σ̄, bounded above, with bounded derivatives, and such that
F (0) = 0 and F ′ (0) = 1.
Note that with this normalization for the function F
it will not appear explicitly in the price approximation in Proposition 3.1 below as
further properties are not important in that context. Moreover, then the filtration Ft
generated by (Bt , Wt ) is also the one generated by Xt . Indeed, it is equivalent to the
one generated by (Wt∗ , Wt ), or (Wt∗ , ZtH ). Since F is one-to-one, it is equivalent to
the one generated by (Wt∗ , σt ). Since σ̄ + F is positive-valued, it is equivalent to the
one generated by (Wt∗ , σt2 ), or Xt .
We aim at computing the option price defined as the martingale
(3.4)
Mt = E h(XT )|Ft ,
where h is a smooth function with bounded derivatives apart from a finite set of
points where it may have a jump discontinuity in its derivative. Note that the proof
in this section will be given for the case with h smooth and bounded. However, as we
(0)
only need to control the function Qt (x) defined below rather than h the argument
can be extended from the smooth case to the situation with jump discontinuity in
the derivative which is relevant in the case with a call payoff. We carry out this
generalization explicitly in Section 4.
The idea of the proof that we present below is to construct an approximation for
Mt which has the correct terminal condition and which up to small (order δ 2 ) terms
is a martingale. It then follows that we have a price approximation to O(δ 2 ).
We introduce the operator
1
LBS (σ) = ∂t + σ 2 x2 ∂x2 .
2
(3.5)
The following proposition gives the first-order correction to the expression of the
martingale Mt when δ is small.
Proposition 3.1. When δ is small, we have
Mt = Qt (Xt ) + O(δ 2 ),
(3.6)
(0)
(1)
(0)
Qt (x) = Qt (x) + δσ̄φt x2 ∂x2 Qt (x) + δρQt (x),
(3.7)
where
(0)
Qt (x) is deterministic and given by the Black-Scholes formula with constant volatility σ̄,
(0)
(0)
LBS (σ̄)Qt (x) = 0,
QT (x) = h(x),
(3.8)
φt is the random component
hZ
φt = E
T
t
9
i
ZsH ds|Ft ,
(3.9)
(1)
and Qt (x) is the deterministic correction
(0)
(1)
Qt (x) = σ̄ 2 x∂x x2 ∂x2 Qt (x) Dt,T ,
with Dt,T defined by
3
τ H+ 2 n
1−
D(τ ) =
Γ(H + 52 )
Dt,T = D(T − t),
Z
aτ
0
e−v 1 −
(3.10)
v H+ 23 o
dv .
aτ
(3.11)
(1)
The correction Qt solves the problem in (3.16) below. The function D(τ ) derives
from solving this problem and is:
Z τ
(τ − u)K(u)du,
D(τ ) =
0
it is discussed in more detail in Lemma A.2 in Appendix A.
Note that the stochastic volatility process we have introduced in Eq. (3.2) is a
stationary power-law process. As a consequence of our modeling we have in particular
that φt is a Gaussian Ft -measurable process, it reflects the influence of the past on
the future stochastic volatility path conditioned on the present. We next present
the proof of Proposition 3.1 and remark that in the analytic framework that we set
forth, exploiting the “ε-martingale decomposition” [27], the cases with H < 1/2 and
H > 1/2 can be treated in a uniform way.
The proof we present below holds for general Gaussian processes Zt with shortand long-range correlations, while the expression to the right in Eq. (3.11) is specific
to the fOU process. We discuss the general Gaussian case and the general expression
(B.4) of D(τ ) in Appendix B.
Proof. For any smooth function qt (x), we have by Itô’s formula
1
dqt (Xt ) = ∂t qt (Xt )dt + x∂x qt (Xt )σt dWt∗ + x2 ∂x2 qt (Xt )σt2 dt
2
= LBS (σt )qt (Xt )dt + x∂x qt (Xt )σt dWt∗ ,
the last term being a martingale. Therefore, by (3.8), we have
(0)
dQt (Xt ) = δσ̄ZtH +
(0)
with Nt
δ 2 δ H 2 2 (0)
(0)
g (Zt ) x ∂x Qt (Xt )dt + dNt ,
2
a martingale,
(0)
dNt
(0)
= x∂x Qt
and g δ (y) is the function
g δ (y) = 2σ̄
(Xt )σt dWt∗ ,
F (δy)2
F (δy) − δy
+
,
δ2
δ2
that can bounded uniformly in δ by
|g δ (y)| ≤ σ̄kF ′′ k∞ + kF ′ k2∞ y 2 .
Note also that in Eq. (3.12) (and below) we use the notation
(0)
(0)
x2 ∂x2 Qt (Xt ) = x2 ∂x2 Qt (x) x=Xt .
10
(3.12)
Let φt be defined by (3.9). We have
φt = ψt −
Z
t
ZsH ds,
(3.13)
i
ZsH ds|Ft ,
(3.14)
0
where the martingale ψt is defined by
hZ
ψt = E
T
0
and it is studied in Appendix A. We can write
(0)
(0)
(0)
ZtH x2 ∂x2 Qt (Xt )dt = x2 ∂x2 Qt (Xt )dψt − x2 ∂x2 Qt (Xt )dφt .
By Itô’s formula:
(0)
(0)
d φt x2 ∂x2 Qt (Xt ) = x2 ∂x2 Qt (Xt )dφt
(0)
+ x∂x x2 ∂x2 Qt (Xt )σt φt dWt∗
(0)
1
+ x2 ∂x2 x2 ∂x2 Qt (Xt )σt2 φt dt
2
(0)
+ x2 ∂x2 ∂t Qt (Xt )φt dt
(0)
+ x∂x x2 ∂x2 Qt (Xt )σt d hφ, W ∗ it
(0)
= x2 ∂x2 Qt (Xt )dφt
(0)
+ x∂x x2 ∂x2 Qt (Xt )σt φt dWt∗
(0)
1
+ δσ̄ZtH + δ 2 g δ (ZtH ) x2 ∂x2 x2 ∂x2 Qt (Xt )φt dt
2
(0)
+ x∂x x2 ∂x2 Qt (Xt )σt d hφ, W ∗ it ,
(0)
where we have used again LBS (σ̄)Qt (x) = 0. We have hφ, W ∗ it = ρ hψ, W it and
therefore
(0)
(0)
d φt x2 ∂x2 Qt (Xt ) = −ZtH x2 ∂x2 Qt (Xt )dt
(0)
1
+ δσ̄ZtH + δ 2 g δ (ZtH ) x2 ∂x2 x2 ∂x2 Qt (Xt )φt dt
2
(0)
+ρ x∂x x2 ∂x2 Qt (Xt )σt d hψ, W it
(1)
+dNt ,
(1)
where Nt
is a martingale,
(1)
dNt
Therefore:
(0)
(0)
= x∂x x2 ∂x2 Qt (Xt )σt φt dWt∗ + x2 ∂x2 Qt (Xt )dψt .
(0)
(0)
d Qt (Xt ) + δσ̄φt x2 ∂x2 Qt (Xt )
(0)
1
= δ 2 σ̄ 2 ZtH + δ 3 σ̄g δ (ZtH ) x2 ∂x2 x2 ∂x2 Qt (Xt )φt dt
2
(0)
(0)
δ2 δ H
+ g (Zt ) x2 ∂x2 Qt (Xt )dt + δσ̄ρ x∂x x2 ∂x2 Qt (Xt )σt d hψ, W it
2
(0)
(1)
+dNt + σ̄δdNt .
(3.15)
11
(1)
The deterministic function Qt
defined by (3.10) satisfies
(0)
(1)
(1)
QT (x) = 0,
LBS (σ̄)Qt (x) = −σ̄ 2 x∂x x2 ∂x2 Qt (x) θt,T ,
(3.16)
where θt,T is such that
d hψ, W it = θt,T dt,
and it is given by (see Lemma A.1):
Z T
Z
θt,T =
K(v − t)dv =
t
T −t
0
K(v)dv.
(3.17)
Applying Itô’s formula
(1)
(1)
(1)
(Xt )σt dWt∗
(1)
δ2
+ g δ (ZtH ) x2 ∂x2 Qt (Xt )dt
2
dQt (Xt ) = LBS (σt )Qt (Xt )dt + x∂x Qt
(1)
= LBS (σ̄)Qt (Xt )dt + δσ̄ZtH
(1)
+ x∂x Qt (Xt )σt dWt∗
(0)
= −σ̄ 2 x∂x x2 ∂x2 Qt (Xt )d hψ, W it
(1)
δ2
(2)
+ δσ̄ZtH + g δ (ZtH ) x2 ∂x2 Qt (Xt )dt + dNt ,
2
(2)
where Nt
is a martingale,
(2)
dNt
Therefore
(1)
= x∂x Qt
(Xt )σt dWt∗ .
(0)
(1)
(0)
d Qt (Xt ) + δσ̄φt x2 ∂x2 Qt (Xt ) + δρQt (Xt ) = dNt − dRt,T ,
(3.18)
where Nt is a martingale,
Nt =
Z
0
t
dNs(0) + σ̄δdNs(1) + ρδdNs(2) ,
(3.19)
and Rt,T is of order δ 2 :
Z T
1
Rt,T = δ 2
σ̄ 2 ZsH + δσ̄g δ (ZsH ) x2 ∂x2 x2 ∂x2 Q(0)
s (Xs )φs ds
2
t
Z
Z T
(0)
δ2 T δ H
2
H
2 2
+
g (Zs ) x ∂x Qs (Xs )ds + δ
σ̄ρ x∂x x2 ∂x2 Q(0)
s (Xs )Zs θs,T ds
2 t
t
Z T
δ
+δ 2
ρσ̄ZsH + ρg δ (ZsH ) x2 ∂x2 Q(1)
(3.20)
s (Xs )ds.
2
t
Then with Qt (x) defined as in Proposition 3.1 we have QT (x) = h(x) because
(1)
= h(x), φT = 0, and QT (x) = 0. Therefore
Mt = E h(XT )|Ft = E QT (XT )|Ft = Qt (Xt ) + E NT − Nt |Ft + E Rt,T |Ft
(3.21)
= Qt (Xt ) + E Rt,T |Ft ,
which completes the proof since E Rt,T |Ft is of order δ 2 .
(0)
QT (x)
12
4. Accuracy with European option. In the derivation above we assumed a
smooth payoff function. Since important classes of payoff functions have non-smooth
payoff we generalize here the proof to such a class by considering a European option.
For a European option h(x) = (x − K)+ we have from Eq. 1.41 in [27]
√
1
x σ̄ T − t
(0)
+
Qt (x) = xΦ √
log
K
2
σ̄ T − t
√
1
x σ̄ T − t
,
(4.1)
−
−KΦ √
log
K
2
σ̄ T − t
where Φ is the cumulative distribution function of the standard normal distribution.
We can see that h is not smooth so that the hypotheses of Proposition 3.1 are not
satisfied. However the conclusions of Proposition 3.1 still hold true
as wenow show.
Proof. One has to show that Rt,T defined by (3.20) satisfies E Rt,T |Ft is of order
δ 2 in Lp for any p and that the local martingale Nt defined by (3.19) is a martingale
(0)
(up to time T ). The problem comes from the fact that the derivatives of Qt (x) blow
up when t → T . However this blow up is not strong as we show below. We first state
a few properties of the deterministic and random terms that appear in the expression
of Rt,T :
(0)
- The deterministic function Qt (x) given by (4.1) satisfies
1
(0)
∂xk Qt (x) ≤ C 1 +
,
k−1
(T − t) 2
for any 1 ≤ k ≤ 4, t ∈ [0, T ], x ∈ (0, ∞), and for some constant C (see Appendix B
in [25]).
- The deterministic quantity Dt,T given by (3.11) satisfies
3
Dt,T ≤ C(T − t)H+ 2 ,
for any t ∈ [0, T ] and for some constant C (see Lemma A.2 and below in Appendix
A).
- The deterministic quantity θt,T defined by (3.17) satisfies
1
θt,T ≤ C(T − t)H+ 2 ,
for any t ∈ [0, T ] and for some constant C (substitute (2.9-2.10) into (3.17)).
- The random component φt defined by (3.9) satisfies
1
E[|φt |p ] p ≤ Cp (T − t),
for any t ∈ [0, T ] and for some constant Cp for any p > 0 (apply Lemma A.3 in
Appendix A and use the fact that φt is Gaussian).
- The random process ZtH satisfies
1
E[|ZtH |p ] p ≤ Cp ,
for any t ∈ [0, T ] and for some constant Cp for any p > 0 (use the fact that ZtH is
2
Gaussian, stationary, with mean zero and variance σou
).
(1)
As a consequence, the deterministic function Qt (x) satisfies
1
k
3
(1)
|∂xk Qt (x)| ≤ C (T − t)H+ 2 + (T − t)H+ 2 − 2 1 + x3 ,
13
for any 1 ≤ k ≤ 2, t ∈ [0, T ], x ∈ (0, ∞), and for some constant C.
Using (3.20) and the previous estimates we find that, for any p > 0, there exists a
constant Cp such that
Z T
1
1
1
1
1
E[|Rt,T |p ] p ≤ Cp δ 2
(T − s)− 2 + (T − s)− 2 + (T − s)H− 2 + (T − s)H− 2 ds
t
1
1
2
≤ Cp δ (T − t) 2 + (T − t)H+ 2 ,
for any δ ∈ (0, 1) and t ∈ [0, T ], which shows the desired result for Rt,T .
(j)
Moreover, the local martingales Nt in (3.19) are continuous square-integrable martingales up to time T whose brackets are
D
E
(j)
d N (j) = Nt dt, j = 0, 1, 2,
t
2
(0)
(0)
Nt = σt x∂x Qt (Xt ) ,
2
(0)
(1)
Nt = x∂x x2 ∂x2 Qt (Xt )σt φt
(0)
(0)
+2ρθt,T x∂x x2 ∂x2 Qt (Xt )σt φt x2 ∂x2 Qt (Xt )
(0)
2 2
+ x2 ∂x2 Qt (Xt ) θt,T
,
2
(1)
(2)
Nt = σt x∂x Qt (Xt ) ,
(j)
where the Nt are uniformly bounded with respect to t ∈ [0, T ] in Lp for any p, which
concludes the proof.
5. The implied volatility. We now compute and discuss the implied volatility associated with the price approximation given in Proposition 3.1. This implied
volatility is the volatility that when used in the constant volatility Black-Scholes
pricing formula gives the same price as the approximation, to the order of the approximation. The implied volatility in the context of the European option introduced in
the previous section is then given by
h
σ̄
log(K/Xt ) i
φt
+ O(δ 2 ).
(5.1)
+ δρDt,T
+
It = σ̄ + δ
T −t
2(T − t)
σ̄(T − t)2
The first two terms can be combined and rewritten as (up to terms of order δ 2 ):
i 21
h 1 Z T
φt
σ̄ + δ
(5.2)
=E
σs2 ds|Ft + O(δ 2 ).
T −t
T −t t
When a(T − t) ≪ 1 the implied volatility is random and we have (see Lemma
A.3) and Eq. (A.5) :
It = σ̄ + δZtH + δ
h σ̄
log(K/Xt ) i
1
ρ
2 +H +
.
(T
−
t)
1
Γ(H + 25 ) 2
σ̄(T − t) 2 −H
(5.3)
Note that, for H ∈ (0, 1/2), the implied volatility blows up at small time-tomaturity T − t. Note, moreover that the result above is valid in the asymptotic
regime δ ≪ 1. Indeed, for σ̄ being an order one strictly positive quantity the implied
volatility in Eq. (5.3) is strictly positive for δ small enough.
1
When a(T − t) ≫ 1, the quantity Dt,T is of order (T − t)H+ 2 and is deterministic
(by Lemma A.2), while the fluctuations of φt are of order (T − t)H at most and are
14
therefore negligible (by Lemma A.3). As a consequence, when a(T − t) ≫ 1, we can
write the implied volatility as:
It = σ̄ + δ
h σ̄
log(K/Xt ) i
ρ
H− 12
+
(T
−
t)
.
3
aΓ(H + 32 ) 2
σ̄(T − t) 2 −H
(5.4)
Note that, for H ∈ (1/2, 1), the implied volatility blows up at large time-tomaturity T − t.
We remark that the factors multiplying the square brackets
in Eqs. (5.3) and (5.4) are slightly modified in the general case when Zt is a general
Gaussian process, see Appendix B.
6. A slow volatility factor. We show in this section that the approach developed in this paper can be applied to other stochastic volatility models. Here we
consider the following model
σt = F (Ztδ,H ),
(6.1)
where F is a smooth, positive-valued function, bounded away from zero, with bounded
derivatives, and Ztδ,H is a rescaled fOU process:
dZtδ,H = δ H dWtH − δaZtδ,H dt,
(6.2)
whose natural time scale is 1/δ. It has the form
Z t
Ztδ,H = δ H
e−δa(t−s) dWsH .
(6.3)
−∞
Its moving-average integral representation is
Z t
Kδ (t − s)dWs ,
Ztδ,H =
−∞
1
Kδ (t) = δ 2 K(δt),
(6.4)
where K is defined by (2.8). In particular its variance is σou defined by (2.5), independently of δ. This model is therefore characterized by strong but slow fluctuations of
the volatility. If the price of the risky asset follows the stochastic differential equation
(3.1), we get a result similar to Proposition 3.1.
Proposition 6.1. When δ is small, denoting σ0 = F (Z0δ,H ) and p0 = F ′ (Z0δ,H ),
the option price (3.4) is of the form
Mt = Qt (Xt ) + O(δ 2H ),
(6.5)
(0)
(1)
(0)
Qt (x) = Qt (x) + σ0 p0 φδt x2 ∂x2 Qt (x) + δ H ρp0 Qt (x),
(6.6)
where
(0)
Qt (x) is given by the Black-Scholes formula with constant volatility σ0 ,
(0)
LBS (σ0 )Qt (x) = 0,
(0)
QT (x) = h(x),
(6.7)
φδt is the random component
hZ
φδt = E
T
t
i
Zsδ,H − Z0δ,H ds|Ft ,
15
(6.8)
(1)
and Qt (x) is the correction
(0)
(1)
Qt (x) = σ02 x∂x x2 ∂x2 Qt (x) Dt,T ,
with Dt,T defined by
(6.9)
3
Dt,T =
(T − t)H+ 2
.
Γ(H + 52 )
(6.10)
We remark that we indeed can expect the situation with a slow volatility factor to
behave qualitatively as the situation with small volatility fluctuations in Proposition
3.1 from the point of view of the effect the medium roughness. This follows since we
have from self-similarity of fractional Brownian motion that in distribution
d
δWtH = WδH1/H t .
However, we have
d
δZtH |a=a′ = ZδH1/H t |a=δ1/H a′ ,
and thus the models (small volatility fluctuations versus slow) differ both in a strong
sense and in distribution. Moreover, the models have different interpretations from
the modeling viewpoint with for instance a different skewness mechanism. Note in
particular that this difference manifests itself in that for fixed Hurst coefficient H the
magnitude of both the correction and the error terms, deriving in particular from the
modeling of correlation, have a different scaling in δ for the two models. For instance
for small Hurst exponent H we may expect, for given δ, the correction (and also the
error term) to be relatively larger in the case of the slow volatility factor. The random
correction φδt is of order δ H . More exactly it is a zero-mean Gaussian random variable
with variance
Z
H+ 12
δ 2 δ 2H T 2+2H ∞ h
t
1
1− +v
E (φt ) =
− v H+ 2
3 2
T
Γ(H + 2 ) 0
t
1
t H− 21 i2
H+
v−
dv + O(δ 2H+1 ),
(6.11)
− 1−
T
2
T +
for t ∈ [0, T ].
Proof. We note that
σt = σ0 + p0 (Ztδ,H − Z0δ,H ) + gtδ ,
where gtδ = F (Ztδ,H ) − F (Z0δ,H ) − F ′ (Z0δ,H )(Ztδ,H − Z0δ,H ) and therefore
1 ′′
kF k∞ (Ztδ,H − Z0δ,H )2 .
2
|gtδ | ≤
We have
E (Ztδ,H − Z0δ,H )2 =
Z
0
δt
K(s)2 ds +
Z
0
∞
2
K(δt + s) − K(s) ds,
which is of order δ 2H :
2
(δt)2H + o(δ 2H ).
E (Ztδ,H − Z0δ,H )2 = σH
16
Therefore gtδ is bounded in Lp for any p by a quantity of order δ 2H . We can then
follow the same proof as the one of Proposition 3.1. The term
Z τ
δ
(τ − u)Kδ (u)du,
Dt,T =
0
is given by
3
δ
Dt,T
= δH
(T − t)H+ 2
+ O(δ 2H ).
Γ(H + 52 )
The variance of the correction φδt is
E (φδt )2 =
Z tZ
0
t
T
Kδ (s − u)ds
2
du +
Z
0
−∞
Z
t
T
Kδ (s − u) − Kδ (−u)ds
2
du,
which in turn gives (6.11).
Proceeding as in the case of the small-amplitude stochastic volatiliy model, we
find that the implied volatility in the context of the European option is given by
It = σ0 + p0
hσ
log(K/Xt ) i
φδt
ρp0
0
H+ 21
+ O(δ 2H ). (6.12)
+
+ δH
(T
−
t)
1
T −t
Γ(H + 52 ) 2
σ0 (T − t) 2 −H
The first two terms can be combined and rewritten as (up to terms of order δ 2H ):
σ0 + p0
i 21
h 1 Z T
φδt
=E
σs2 ds|Ft + O(δ 2H ).
T −t
T −t t
(6.13)
7. Conclusion. We have presented an analysis of the European option price
when the volatility is stochastic and has correlations that decay as a fractional power
of the time offset. The stochastic volatility model is defined in terms of a fractional
Ornstein Uhlenbeck process with Hurst exponent H and the analysis is carried out
when the typical amplitude of the volatility fluctuations is relatively small. Two
situations are differentiated. First the situation when H ∈ (0, 1/2) which corresponds
to a “short-range” dependent process that is rough on short scales with correlations
that decay very rapidly, faster than linear decay, at the origin. Second the situation
when H ∈ (1/2, 1) so that the correlations decay relatively slowly at large scales
and then the volatility correlations are not integrable. We use a martingale method
approach to derive a general expression for the Black-Scholes price covering the two
cases. In the short-range case the rough behavior on short scales gives rise to an
implied volatility that diverges as the time to maturity goes to zero. In the longrange case the slow decay in the correlations gives a term structure of the implied
volatility that diverges as time to maturity goes to infinity. The main result we have
presented is specific in the sense that a particular stochastic volatility model has been
addressed, however, as we illustrate the framework can be adapted to related models
as long as some central covariance terms can be computed. We illustrate this by
considering a model with slow, but order one, volatility fluctuations and derive the
associated fractional implied volatility term structure.
Appendix A. Technical lemmas. In this appendix we state and prove a few
technical lemmas related to some central quantities of interest that are used in the
derivation of the price in Sections 3 and 5.
17
The martingale ψt is defined for any t ∈ [0, T ] by (3.14). It is used in the proof
of Proposition 3.1 and it has the following properties.
Lemma A.1. (ψt )t∈[0,T ] is a Gaussian square-integrable martingale and
Z T −t
Z T −t
2
d hψ, W it =
K(s)ds dt,
d hψit =
K(s)ds dt.
(A.1)
0
0
Proof. For t ≤ s, the conditional distribution of ZsH given Ft is Gaussian with
mean
Z t
K(s − u)dWu ,
(A.2)
E ZsH |Ft =
−∞
and deterministic variance given by
Var ZsH |Ft =
Therefore we have
Z t
Z
ψt =
ZsH ds +
0
=
t
Z
0
ds
0
=
−∞
Z
s
−∞
hZ T
0
s−t
K(u)2 du.
0
T
t
Z
Z
E ZsH |Ft ds
K(s − u)dWu +
Z
T
dt
t
Z
i
K(s − u)dt dWu +
0
Z
t
−∞
thZ T
u
K(s − u)dWu
i
K(s − u)dt dWu .
This gives
d hψ, W it =
Z
t
T
K(s − t)ds dt,
d hψit =
Z
t
T
K(s − t)ds
2
dt,
as stated in the Lemma.
We define the deterministic component
Dt,T = hψ, W iT − hψ, W it ,
(A.3)
that appears in Equation (3.10). It has the following properties.
Lemma A.2. Dt,T is a deterministic function of T − t and it is given by
Z τ
(τ − u)K(u)du.
Dt,T = D(T − t),
D(τ ) =
(A.4)
0
The function D can be written as (3.11) and it has the following behavior:
For aτ ≪ 1,
1
H+ 32
H+ 32
+
o
(aτ
)
.
D(τ ) =
(aτ
)
3
Γ(H + 52 )aH+ 2
For aτ ≫ 1,
D(τ ) =
1
Γ(H +
3 H+ 23
2 )a
1
1
(aτ )H+ 2 + o (aτ )H+ 2
Finally, we consider the random process φt defined by (3.9).
Lemma A.3.
18
.
(A.5)
(A.6)
1. φt is a zero-mean Gaussian process with variance
Z ∞ Z T −t
2
Var(φt ) =
K(s + u)ds du.
0
0
2. There exists a constant C (that depends on H) such that the variance of φt
can be bounded by
Var(φt ) ≤ C (T − t)2H ∧ (T − t)2 .
(A.7)
3. φt is approximately equal to (T − t)ZtH for small T − t:
2 i
h φ
T −t→0
t
− ZtH
−→ 0.
E
T −t
(A.8)
Proof. We can express the variance of φt as:
Z T −t Z T −t
ds
Var(φt ) =
ds′ Cov E ZsH |F0 , E ZsH′ |F0 ,
0
0
which gives the first item since
Cov E ZsH |F0 , E ZsH′ |F0 =
Z
0
−∞
K(s − u)K(s′ − u)du.
Furthermore
Z
T −t
Var(φt ) ≤
T −t
≤
Z
0
0
1/2 2
ds
Var E ZsH |F0
∞
Z
s
2H
≤ C (T − t)
K(u)2 du
1/2
ds
2
∧ (T − t)2 ,
which gives the second item of the lemma.
Similarly, we have
2 i 1 Z T −t
h φ
1/2 2
t
≤
,
− ZtH
dsVar E ZsH |F0 − Z0H
E
T −t
T −t 0
and
E ZsH |F0 − Z0H =
Z
0
−∞
K(s − u) − K(−u) dWu ,
so that
h φ
2 i 1 Z T −t h Z ∞
2 i 2
t
E
≤
K(s + v) − K(v) dv ds .
− ZtH
T −t
T −t 0
0
2
R∞
As s → 0, we have 0 K(s+v)−K(v) dv → 0 by Lebesgue’s dominated convergence
theorem (remember K ∈ L2 ), which gives the third item.
Appendix B. Extension to a general stochastic volatility model. In the
paper, we model the volatility as a bounded function of a fOU process. In fact it is
19
straightforward to extend all the results to a volatility model that is a bounded function of a stationary Gaussian process whose correlation properties are qualitatively
similar as the ones of a fOU process. In this appendix we consider the situation when
the volatility is
σt = σ̄ + F (δZt ),
for Zt a stationary Gaussian process with mean zero of the form
Z t
Zt =
K(t − s)dWs ,
(B.1)
(B.2)
−∞
where Wt is a standard Brownian motion and K ∈ L2 (0, ∞) is a general kernel instead
of the specific kernel (2.8) corresponding to a fOU. Then the Gaussian process Zt has
mean zero, variance
Z ∞
2
σZ
=
K2 (u)du,
(B.3)
0
and covariance
E[Zt Zt+s ] =
Z
∞
0
K(u)K(u + s)du.
As before (above Proposition 3.1), the function F is assumed to be one-to-one, smooth,
bounded from below by a constant larger than −σ̄, with bounded derivatives, and such
that F (0) = 0 and F ′ (0) = 1. Proposition 3.1 then holds true, with the function D
defined by
Z τ
(τ − u)K(u)du,
(B.4)
D(τ ) =
0
and the implied volatility in the context of the European option is still given by (5.1)
with Dt,T = D(T − t). The behavior of the function D is determined by the one of
the kernel K and we consider in more detail two cases corresponding respectively to
long- and short-range correlations:
1. There exists cZ 6= 0 such that
3
K(t) = cZ tH− 2 1 + o(1) as t → ∞.
(B.5)
If H ∈ (1/2, 1) this implies that K is not integrable at infinity and, as we will
see below (see Lemma B.1), the covariance function of Zt has a tail behavior
similar to that of a fOU at infinity. In other words, Zt possesses long-range
correlation properties, and the implied volatility has the same form (5.4) as
in the case of a fOU with Hurst index H, with cZ Γ(H − 1/2)/Γ(H + 3/2)
instead of 1/[aΓ(H + 3/2)].
2. There exists dZ 6= 0 such that
1
K(t) = dZ tH− 2 1 + o(1) as t → 0.
(B.6)
If H ∈ (0, 1/2) this implies that K is singular at zero and, as we will see
below (see Lemma B.2), the covariance function of Zt has a behavior similar
to that of a fOU at zero. In other words, Zt possesses short-range correlation
properties, and the implied volatility has the same form (5.3) as in the case of
a fOU with Hurst index H, however, with dZ Γ(H +1/2)/Γ(H +5/2) replacing
1/Γ(H + 5/2).
20
Lemma B.1. We assume (B.5).
1. If H ∈ (1/2, 1), then the covariance function of Zt satisfies
E[Zt Zt+s ] = kZ s2H−2 1 + o(1) as s → ∞,
(B.7)
with
kZ = c2Z
Γ(2 − 2H)Γ(H − 21 )
Γ(H − 21 )2
2
.
=
c
Z
2 sin(πH)Γ(2H − 1)
Γ( 23 − H)
(B.8)
2. If H ∈ (1/2, 1), then the function D(τ ) defined by (B.4) satisfies
D(τ ) = cZ
Γ(H − 21 ) H+ 1
2 1 + o(1)
as τ → ∞.
3 τ
Γ(H + 2 )
(B.9)
If Zt is the fOU process (2.4), we have cZ = 1/[aΓ(H − 1/2)]. In this case, we can
2 2H−2
check that kZ = a−2 /[2 sin(πH)Γ(2H − 1)] = σou
a
/Γ(2H − 1), which confirms
that (B.7-B.8) give (2.12), while (B.9) gives (A.6).
Proof. We denote
Z ∞
Z ∞
3
3
˜ = c2
K(u)K(u + s)du and C(s)
C(s) = E[Zt Zt+s ] =
uH− 2 (u + s)H− 2 du.
Z
0
0
˜ = kZ s2H−2 with
We can check that C(s)
kZ =
c2Z
Z
0
∞
3
3
uH− 2 (1 + u)H− 2 du = c2Z
Γ(2 − 2H)Γ(H − 21 )
.
Γ( 23 − H)
We now show that C(s)− C̃(s) goes to zero as s → ∞ faster than s2H−2 . Let ε ∈ (0, 1).
There exists S ε such that |K(t)t−H+3/2 − cZ | ≤ ε for any t ≥ S ε . We have for any
s ≥ S ε:
s
2−2H
˜
C(s) − C(s)
≤ s2−2H
+s
Z
Sε
0
2−2H
Z
∞
Z
∞
Sε
+s2−2H
Sε
Z
3
3
K(u)K(u + s) − c2Z uH− 2 (u + s)H− 2 du
3
|K(u)||K(u + s) − cZ (u + s)H− 2 |du
3
3
|cZ |(u + s)H− 2 |K(u) − cZ uH− 2 |du
Sε
3
3
K(u)K(u + s) − c2Z uH− 2 (u + s)H− 2 du
0
Z ∞
3
3
+s2−2H ε(2|cZ | + ε)
(u + s)H− 2 uH− 2 du.
≤s
2−2H
0
As s → ∞ the first term of the right-hand side goes to zero by Lebesgue dominated
convergence theorem because (2 − 2H) + (H − 3/2) < 0. This gives
Z ∞
3
3
˜
(u + 1)H− 2 uH− 2 du.
lim sup s2−2H C(s) − C(s)
≤ ε(2|cZ | + ε)
s→∞
0
Since this holds true for any ε ∈ (0, 1), this proves (B.7).
21
We denote
D̃(τ ) =
Z
τ
0
3
(τ − u)cZ uH− 2 du,
which is given by
D̃(τ ) =
Γ(H − 12 ) H+ 1
cZ
H+ 21
2.
τ
τ
=
c
Z
H 2 − 41
Γ(H + 32 )
Let ε ∈ (0, 1). As mentioned above, there exists S ε such that |K(t)t−H+3/2 − cZ | ≤ ε
for any t ≥ S ε . We have then for any τ ≥ S ε :
1
1
τ −H− 2 D(τ ) − D̃(τ ) ≤ τ −H− 2
+τ
Z
−H− 12
Sε
0
ε
Z
3
(τ − u) K(u) − cZ uH− 2 du
τ
Sε
3
(τ − u)uH− 2 du.
As τ → ∞ the first term of the right-hand side goes to zero by Lebesgue dominated
convergence theorem because −(H + 1/2) + 1 < 0. This gives
lim sup τ
τ →∞
−H− 12
D(τ ) − D̃(τ ) ≤ ε
Z
0
1
3
(1 − u)uH− 2 du.
Since this holds true for any ε ∈ (0, 1), this proves (B.9).
Lemma B.2. We assume (B.6).
1. If H ∈ (0, 1/2) and if K satisfies the two technical conditions:
(CB.2.1) K is integrable and Lipschitz on (1, ∞).
(CB.2.2) There exist functions k1 (t) and k2 (s) such that for all t, s ∈ (0, 1) we
have |K̃(t + s) − K̃(t)| ≤ k1 (t)k2 (s), where K̃(t) = K(t) − dZ tH−1/2 ,
k1 ∈ L2 (0, 1), and lims→0 s−H k2 (s) = 0.
Then the covariance function of Zt satisfies
2
E[Zt Zt+s ] = σZ
− qZ s2H + o(s2H ) as s → 0,
(B.10)
with
Γ(H + 21 )2
d2Z
,
2 Γ(2H + 1) sin(πH)
Z ∞
2
σZ
=
K2 (u)du.
qZ =
(B.11)
(B.12)
0
2. For any H ∈ (0, 1), the function D(τ ) defined by (B.4) satisfies
D(τ ) = dZ
Γ(H + 21 ) H+ 3
2 1 + o(1)
as τ → 0.
5 τ
Γ(H + 2 )
(B.13)
The condition (CB.2.1) gives some control of K away from the origin, and this
specific condition can be relaxed. The necessary condition is that
Z ∞
2
K(u + s) − K(u) du
s−2H
1
22
goes to zero as s → 0 (see the proof below).
The condition (CB.2.2) means that the remainder K̃(t) should be small enough
near the origin. A sufficient condition for (CB.2.2) is that K̃ is α-Hölder continuous
over (0, 2) for some α > H. Then (CB.2.2) is fulfilled with k1 (t) = c and k2 (s) = k̃α sα ,
for some constant c.
If Zt is the fOU process (2.4), then K is integrable and Lipschitz on (1, ∞) and we
Rt
have dZ = 1/Γ(H + 1/2) and K̃(t) = −[a/Γ(H + 1/2)] 0 (t − s)H−1/2 e−as ds, which is
(H + 1/2)-Hölder continuous over (0, 2): |K̃(t + s) − K̃(t)| ≤ [2a/Γ(H + 3/2)]sH+1/2 .
2 2H
In this case we can check that qZ = 1/[2Γ(2H + 1) sin(πH)] = σou
a /Γ(2H + 1),
2
2
moreover we have then σZ = σou , which confirms that (B.10-B.12) give (2.11), while
(B.13) gives (A.5).
Proof. We can write
1
2
E[Zt Zt+s ] = σZ
− Q(s),
Q(s) = E (Zt+s − Zt )2 .
2
We have Q(s) = Q1 (s) + Q2 (s) with
Z
Z
2
1 s
1 ∞
K(u + s) − K(u) du,
Q2 (s) =
K(u)2 du.
Q1 (s) =
2 0
2 0
The idea is to approximate these two functions by their versions when dZ tH−1/2
replaces K(t). We denote
Z ∞
Z s
1
1 2
d2
d2
Q̃2 (s) = Z
(u + s)H− 2 − uH− 2 du,
u2H−1 du.
Q̃1 (s) = Z
2 0
2 0
We can check that Q̃1 (s) + Q̃2 (s) = qZ s2H with
Z
Z
Γ(H + 21 )2
d2Z ∞ H− 12
d2
d2Z 1 2H−1
H− 21 2
u
.
qZ =
u
du = Z
− (1 + u)
du +
2 0
2 0
2 Γ(2H + 1) sin(πH)
We now show that Q1 (s) − Q̃1 (s) goes to zero as s → 0 faster than s2H . We have
2s−2H Q1 (s) − Q̃1 (s)
Z 1
2
1
1 2
−2H
≤s
K(u + s) − K(u) − d2Z (u + s)H− 2 − uH− 2 du
0
Z ∞
Z ∞
2
1
1 2
−2H 2
(u + s)H− 2 − uH− 2 du + s−2H
+s
dZ
K(u + s) − K(u) du
1
≤ 2|dZ |s−2H
+s−2H
+s−2H
≤ 2|dZ |
Z0 ∞
hZ
+s−2H
1
Z
1
hZ
1
∞
1
(u + s)
0
0
+2s1−2H LK
2
du
1
i1/2 h Z
Z
0
∞
2 i1/2
K̃(u + s) − K̃(u) du
1
1
(u + s)H− 2 − uH− 2
1
K(u + s) − K(u) |K(u + s)| + |K(u)| du
H− 21
(u + 1)
1
−u
H− 21
2
K̃(u + s) − K̃(u) du + s−2H d2Z
0
Z
H− 12
−u
H− 12 2
Z
i1/2 h
−2H
du
s
0
2
K̃(u + s) − K̃(u) du + d2Z
Z
∞
0
|K(u)|du,
23
Z
∞
1/s
1
2
du
2 i1/2
K̃(u + s) − K̃(u) du
1
1
(u + 1)H− 2 − uH− 2
2
du
where LK is the Lipschitz constant of K over (1, ∞). As s → 0 the third term of the
right-hand side goes to zero because the integral is convergent and the fourth term
goes to zero because 1 − 2H > 0. The first and second terms go to zero because
Z 1
Z 1
2
K̃(u + s) − K̃(u) du ≤ s−2H k2 (s)2
s−2H
k1 (u)2 du,
0
0
k1 ∈ L2 (0, 1), and s−H k2 (s) → 0 as s → 0. Therefore
lim s−2H Q1 (s) − Q̃1 (s) = 0.
s→0
We now show that Q2 (s) − Q̃2 (s) goes to zero as s → 0 faster than s2H . Let ε ∈ (0, 1).
There exists S ε such that |K(t)t−H+1/2 − dZ | ≤ ε for any t ≤ S ε . We have for any
s ≤ S ε:
Z s
1
1
2s−2H Q2 (s) − Q̃2 (s) ≤ s−2H
K(u) − dH uH− 2 |K(u)| + |dZ |uH− 2 du
0
Z s
(2|dZ | + ε)ε
.
u2H−1 du ≤
≤ s−2H ε(2|dZ | + ε)
2H
0
Since this holds true for any ε ∈ (0, 1), we have
lim s−2H Q2 (s) − Q̃2 (s) = 0,
s→0
which completes the proof of (B.10).
We denote
D̃(τ ) = dZ
Z
0
τ
1
(τ − u)uH− 2 du,
which is given by
D̃(τ ) =
Γ(H + 21 ) H+ 3
dZ
H+ 32
2.
=
d
τ
τ
Z
(H + 21 )(H + 23 )
Γ(H + 52 )
Let ε ∈ (0, 1). There exists S ε such that |K(t)t−H+1/2 − dZ | ≤ ε for any t ≤ S ε . We
have for any τ ≤ S ε :
Z τ
3
1
3
τ −H− 2 D(τ ) − D̃(τ ) ≤ τ −H− 2 ε
(τ − u)uH− 2 du.
0
This gives
3
lim sup τ −H− 2 D(τ ) − D̃(τ ) ≤ ε
τ →0
Z
0
1
1
(1 − u)uH− 2 du.
Since this holds true for any ε ∈ (0, 1), this proves (B.13).
REFERENCES
[1] Y. Aı̈t-Sahalia, J. Fan, and J. Li, Testing for jumps in a discretely observed process, Ann.
Statist. 37 (2009), pp. 184–222.
24
[2] Y. Aı̈t-Sahalia and J. Jacod, The leverage effect puzzle: Disentangling sources of bias at high
frequency, Journal of Financial Economics 109 (2013), pp. 224–249.
[3] E. Alòs, J. A. León, and J. Vives, On the short-time behavior of the implied volatility for
jump-diffusion models with stochastic volatility, Finance Stoch. 11 (2007), pp. 571–589.
[4] O. E. Barndorff-Nielsen, F. E. Benth, and A. E. D. Veraart, Modelling energy spot prices by
volatility modulated Lévy driven Volterra processes, Bernoulli 19 (2013), pp. 80–845.
[5] C. Bayer, P. Friz, and J. Gatheral, Pricing under rough volatility, Quantitative Finance 16
(2016), pp. 887–904.
[6] H. Berestycki, J. Busca, and I. Florent, Computing the implied volatility in stochastic volatility
models, Comm. Pure Appl. Math. 57 (2004), pp. 1352–1373.
[7] F. Biagini, Y. Hu, B. Øksendal, and T. Zhang, Stochastic Calculus for Fractional Brownian
Motion and Applications, Springer, London, 2008.
[8] T. Bollerslev, D. Osterrieder, N. Sizova, and G. Tauchen, Risk and return: Long-run relations,
fractional cointegration, and return predictability, Journal of Financial Economics 108
(2013), pp. 409–424.
[9] P. Carr and L. Wu, What type of processes underlies options? A simple robust test, Journal
of Finance 58 (2003), pp. 2581–2610.
[10] C. Cheridito, H. Kawaguchi, and M. Maejima, Fractional Ornstein-Uhlenbeck processes, Electronic Journal of Probability 8 (2003), pp. 1–14.
[11] A. Chronopoulou and F. G. Viens, Estimation and pricing under long-memory stochastic
volatility, Annals of Finance 8 (2012), pp. 379–403.
[12] A. Chronopoulou and F. G. Viens, Stochastic volatility models with long-memory in discrete
and continuous time, Quantitative Finance 12 (2012), pp. 635–649.
[13] F. Comte, L. Coutin, and E. Renault, Affine fractional stochastic volatility models, Annals of
Finance 8 (2010), pp. 337-378.
[14] F. Comte and E. Renault, Long memory in continuous-time stochastic volatility models, Mathematical Finance 8 (1998), pp. 291–323.
[15] R. Cont, Long range dependence in financial markets, in Fractals in Engineering, edited by J.
Lévy Véhel and Evelyne Lutton, Springer, London, 2005, pp. 159–179.
[16] S. Corley, J. Lebovits and J. Lévy Véhel, Multifractional Stochastic volatility models, Mathematical Finance 24 (2014), pp. 364-402.
[17] L. Coutin, An introduction to (stochastic) calculus with respect to fractional Brownian motion,
in Séminaire de Probabilités XL, Lecture Notes in Mathematics, Vol. 1899, Springer, 2007,
pp. 3–65.
[18] P. Doukhan, G. Oppenheim, and M. S. Taqqu, Theory and Applications of Long-Range Dependence, Birkhäuser, Boston, 2003.
[19] D. Duffie, R. Pan, and K. Singleton, Transformation analysis and asset pricing for affine jumpdiffusion, Econometrica 68 (2000), pp. 1343–1376.
[20] R. F. Engle, and A. J. Patton, What good is a volatility model?, Quantitative Finance 1 (2001),
pp. 237–245.
[21] J. E. Figueroa-López and S. Olafsson, Short-time expansions for close-to-the-money options
under a Lévy jump model with stochastic volatility, Finance and Stochastics 20 (2016),
pp. 219–265.
[22] H. Fink, C. Klüppelberg, and M. Zähle, Conditional distributions of processes related to fractional Brownian motion, J. Appl. Prob. 50 (2013), pp. 166–183.
[23] M. Forde and H. Zhang, Asymptotics for rough stochastic volatility and Lévy models, preprint
available at http://www.mth.kcl.ac.uk/˜fordem/.
[24] J. P. Fouque, G. Papanicolaou, and K. R. Sircar, Derivatives in Financial Markets with Stochastic Volatility, Cambridge University Press, Cambridge, 2000.
[25] J. P. Fouque, G. Papanicolaou, K. R. Sircar, and K. Solna, Singular perturbations in option
pricing, SIAM J. Appl. Math., 63 (2003), pp. 1648–1665.
[26] J. P. Fouque, G. Papanicolaou, K. R. Sircar, and K. Solna, Timing the smile, The Wilmott
Magazine, March (2004).
[27] J. P. Fouque, G. Papanicolaou, K. R. Sircar, and K. Solna, Multiscale Stochastic Volatility
for Equity, Interest Rate, and Credit Derivatives, Cambridge University Press, Cambridge,
2011.
[28] M. Fukasawa, Asymptotic analysis for stochastic volatility: martingale expansion, Finance and
Stochastics 15 (2011), pp. 635–654.
[29] M. Fukasawa, Short-time at-the-money skew and rough fractional volatility, arXiv:1501.06980.
[30] J. Gatheral, T. Jaisson, and M. Rosenbaum, Volatility is rough, arXiv:1410.3394.
[31] H. Guennoun, A. Jacquier, and P. Roome, Aymptotic behaviour of the fractional Heston model,
arXiv:1411.7653.
25
[32] A. Gulisashvili, F. Viens, and X. Zhang, Small-time asymptotics for Gaussian self-similar
stochastic volatility models, arXiv:1505.05256.
[33] P. Henry-Labordére, Analysis, Geometry, and Modeling in Finance: Advanced Methods in
Option Pricing, Chapman & Hall, Boca Raton, 2009.
[34] S. L. Heston, A closed-form solution for options with stochastic volatility with applicantions to
bond and currency options, The Review of Financial Studies 6 (1993), pp. 327–343.
[35] T. Kaarakka and P. Salminen, On fractional Ornstein-Uhlenbeck processes, Communications
on Stochastic Analysis 5 (2011), pp. 121–133.
[36] R. Lee, The Moment Formula for Implied Volatility at Extreme Strikes, Mathematical Finance
14 (2004), pp. 469–480.
[37] B. B. Mandelbrot and J. W. Van Ness, Fractional Brownian motions, fractional noises and
applications, SIAM Review 10 (1968), pp. 422–437.
[38] R. V. Mendes, M. J. Oliveira, and A. M. Rodrigues, The fractional volatility model: An agentbased interpretation, Physica A 387 (2008), pp. 3987–3994.
[39] R. V. Mendes, M. J. Oliveira, and A. M. Rodrigues, No-arbitrage, leverage and completeness
in a fractional volatility model, Physica A 419 (2015), pp. 470–478.
[40] A. Mijatovic and P. Tankov, A new look at short-term implied volatility in asset price models
with jumps, Mathematical Finance 26 (2016), pp. 149–183.
[41] A. A. Muralev, Representation of franctional Brownian motion in terms of an infinitedimensional Ornstein-Uhlenbeck process, Russ. Math. Surv. 66 (2011), pp. 439–441.
[42] E. Renault and N. Touzi, Option hedging and implicit volatilities in a stochastic volatility
model, Mathematical Finance 6 (1996), pp. 279–302.
[43] C. D. Wang and P. A. Mykland, The estimation of leverage effect with high-frequency data,
Journal of the American Statistical Association 109 (2014), pp. 197–215.
26