Abstract
As the Heston model is not consistent with VIX data in real market well enough, alternative stochastic volatility models including the double-mean-reverting model of Gatheral (in: Bachelier Congress, 2008) have been developed to overcome its limitation. The double-mean-reverting model is a three factor model successfully reflecting the empirical dynamics of the variance but there is no closed form solution for VIX derivatives and SPX options and thus calibration using conventional techniques may be slow. In this paper, we propose a fast mean-reverting version of the double-mean-reverting model. We obtain a closed form approximation for VIX derivatives and show how it is effective by comparing it with the Heston model and the double-mean-reverting model.
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Notes
The data for VIX and its derivatives can be found at the following sites: https://www.cboe.com/products/vix-index-volatility/vix-options-and-futures/vix-index/vix-historical-data, http://cfe.cboe.com/market-data/historical-data, https://datashop.cboe.com.
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Acknowledgements
We thank the anonymous reviewers and the editor for their valuable comments and suggestions to improve the paper. The author J.-H. Kim gratefully acknowledges the financial support of the National Research Foundation of Korea NRF-2017R1A2B4003226.
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Appendix
Appendix
This appendix is devoted to prove the price approximation (3) with the approximation error, stated in Sect. 3, using the asymptotic analysis of Fouque et al. [12]. Without loss of generality, the interest rate r is assumed to zero here (so, \(D\left( \tau \right) \) is omitted), which makes it possible to price VIX futures and options consistently. Once pricing formulas are derived, the original prices can be obtained just by discounting the results.
First, applying the Feynman–Kac theorem (cf. [20]) to \(P^{\epsilon }\), we obtain a singularly perturbed partial differential equation given by
where
Then the expansion \(P^{\epsilon }=P_{0}+\sqrt{\epsilon }P_{1}+\epsilon P_{2}+\cdots \) gives
We have the equation \(\mathcal {L}_{0}P_{0}=0\) from the \(\frac{1}{\epsilon }\)-order term. This equation leads to the following solution (which depends on \(\alpha \)):
for \(1/2<\alpha <1\),
for \(\alpha =1/2\), and
for \(\alpha =1\). Then, from the growth condition (cf. Sect. 3) assumed for the VIX derivative price (2), the above \(c_{1}(t,z)\) must be zero. So, \(P_{0}\) is independent of y. Similarly, the equation from the \(\frac{1}{\sqrt{\epsilon }}\)-order terms gives a result that \(P_{1}\) is also independent of y. Then the following Poisson equation is obtained from the \(\epsilon ^{0}\)-order terms:
Its solvability condition (cf. [12]) is \(\left\langle \mathcal {L}_{2}P_{0}\right\rangle = \left\langle \mathcal {L}_{2}\right\rangle P_{0} = 0\), where \(\left\langle \,.\,\right\rangle \) denotes expectation with respect to the invariant distribution of \(Y_{t}\) (cf. Remark below for the explicit formula of the invariant distribution). Since \(P_{0}\) and the operator \(\mathcal {L}_{2}\) do not depend on y, \(\left\langle \mathcal {L}_{2}\right\rangle P_{0} =0\) leads to
Now, we substitute the expansion of \(P^{\epsilon }\) into (2) and obtain
Letting \(\epsilon \) go to zero, we obtain
where \(\tilde{h}_{0}:=\underset{\epsilon \rightarrow 0}{\lim }h^{\epsilon }\), \(h_{0}:=\int _{0}^{\infty }\tilde{h}_{0}\left( u,\cdot \right) \phi _{v}^{*}\left( u\right) du\), \(\phi _{y,z}\left( \,\cdot \,|Z_{T}=v\right) \) is the conditional density function of \(Y_{T}\) given \(Z_{T}=v\), \(Y_{t}=y\) and \(Z_{t}=z\), \(\phi _{v}^{*}\) is the invariant density function of \(Y_{T}\) given \(Z_{T}=v\), and \(\psi _{z}\) is the density function of \(Z_{T}\) given \(Z_{t}=z\). Here, the bounded convergence theorem (cf. Folland [11]) has been applied to change the limit and the integral. Knowing that the operator \(\mathcal {L}_{2}-\partial _{t}\) is the infinitesimal operator of the CIR process \(Z_{t}\), the Feynman–Kac theorem says that Eq. (9) implies the terminal condition \(P_{0}\left( T,z\right) =h_{0}\left( z\right) \). Also, one can express \(P_{0}\) as a single integral of the Heston price type integrand given by
where
and \(f\left( \nu ;k,\lambda \right) \) is a probability density function of non-central chi-square distribution with \(k=\frac{4c\theta }{\sigma _{z}^{2}}\) degrees of freedom and the non-centrality parameter \(\lambda =\frac{z\mathrm{e}^{-c\tau }}{\gamma }\). Note that
or
where \(\mathrm{VIX}_{T}^{*}=\sqrt{a_{2}^{*}Z_{T}+a_{3}^{*}\theta }\times 100\), \(a_{2}^{*}=\frac{1}{c\varDelta T}\left( 1-\mathrm{e}^{-c\varDelta T}\right) \) and \(a_{3}^{*}=1-a_{2}^{*}\). This means that \(P_{0}\) is exactly the same as the VIX derivative price of the Heston model.
In what follows, we calculate the first-order correction term \(P_{1}\). Because \(\mathcal {L}_{0}P_{2}=0\) is obtained from (6) and (7), \(P_{2}\) is independent of y also. Then, applying the solvability condition to the equation , which comes from the \(\sqrt{\epsilon }\)-order terms, gives
The terminal condition for this PDE is found by utilizing (8). If subtracting \(P_{0}\) from the both sides of equation (8) and dividing it with \(\sqrt{\epsilon }\), we have
Letting \(\epsilon \) go to zero, we obtain
where \(\tilde{h}_{1}:=\underset{\epsilon \rightarrow 0}{\lim }\frac{h^{\epsilon }\left( u,v\right) -\tilde{h}_{0}\left( u,v\right) }{\sqrt{\epsilon }}\) and \(h_{1}:=\int _{0}^{\infty }\tilde{h}_{1}\left( u,\cdot \right) \phi _{v}^{*}\left( u\right) du\). Then we have
In fact, one can extend the results for \(P_0\) and \(P_1\) to all \(P_{i}\) for \(i\ge 2\) by induction and obtain
and they all are independent of y because \(\mathcal {L}_{0}P_{i}=0\) holds. At first glance, it might look strange because VIX derivatives are certainly affected by the process \(Y_t\). However, the perturbation theory used in our model framework may not reflect the current value y of the fast mean-reverting variance directly. Its mean level z (the intermediate-term variance) is a major factor of the price. Recall \(\mathrm{VIX}_{T}^{2}=a_{1}Y_{T}+a_{2}Z_{T}+a_{3}\theta \). For the calibration purpose, this is desirable in the sense that it is difficult to observe the short-term value of volatility whereas it may not be the case with its mean level. Even if there is no explicit dependence of each term \(P_i\) on y, we note that the dependence on the parameters \(\alpha \) and \(\nu \) controlling the process \(Y_t\) can be identified through the invariant distribution \(\phi ^*_z\) which is given by Remark at the end of this appendix.
Now, we explain how to obtain each \(h_{i}\). We first note that \(\tilde{h}_{i}\) is defined in such a way that \(h^{\epsilon }=\tilde{h}_{0}+\sqrt{\epsilon }\tilde{h}_{1}+\epsilon \tilde{h}_{2}+\cdots \) holds, which leads to the idea that \(\tilde{h}_{i}\) could be easily derived by deploying the Talyor expansion associated with \(h^{\epsilon }\). By the definitions of \(a_{1}\) and \(a_{2}\) in Sect, 2, \(a_{1}u+a_{2}v+a_{3}\theta =a_{2}^{*}v+a_{3}^{*}\theta +\left( ca_{2}^{*}\left( v-\theta \right) +\frac{1}{\varDelta T}\left( u-v\right) \right) \epsilon +O\left( \epsilon ^{2}\right) \) for some variables u and v. So, for a given (regularized) payoff H, \(h^{\epsilon }\left( u,v\right) \) can be expanded as follows:
where \(\tilde{H}\left( x\right) :=H\left( 100\sqrt{x}\right) \) is a single variable function. This implies
and \(\tilde{h}_{i}\left( u,v\right) =0\) for every odd number i. So, we obtain \(h_{0}\) and \(h_{2}\) given by
respectively and \(h_{i}\left( v\right) =0\) for every odd number i. Here, \(\int _{0}^{\infty }u\phi _{v}^{*}\left( u\right) du=v\) has been used for \(h_{2}\). It is notable that \(P_{i}=0\) for every odd number i. Particularly, \(P_{1}=0\) and \(P_{3}=0\) improve the accuracy of our approximation. Specific forms of \(h_{i}\) for each VIX derivative are obtained by applying this method to the corresponding payoff H given by
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VIX futures: \(H\left( x\right) =x\)
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VIX call option: \(H\left( x\right) =\left( x-K\right) \varvec{1}_{\left\{ x\ge K\right\} }\)
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VIX put option: \(H\left( x\right) =\left( K-x\right) \varvec{1}_{\left\{ x\le K\right\} }\)
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VIX binary call option: \(H\left( x\right) =\varvec{1}_{\left\{ x\ge K\right\} }\)
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VIX binary put option: \(H\left( x\right) =\varvec{1}_{\left\{ x\le K\right\} }\)
Here, K is the strike of an option.
Next, we discuss the accuracy of the price approximation \(\tilde{P}^{\epsilon }\left( =P_{0}+\epsilon P_{2}\right) \) for the futures. One can do it similarly for the options. For convenience, let \(\hat{P}^{\epsilon }:=\tilde{P}^{\epsilon }+\epsilon ^{2}P_{4}+\epsilon ^{2}\sqrt{\epsilon }P_{5}\), \(R^{\epsilon }:=P^{\epsilon }-\hat{P}^{\epsilon }\) and \(\mathcal {L}^{\epsilon }:=\frac{1}{\epsilon }\mathcal {L}_{0}+\frac{1}{\sqrt{\epsilon }}\mathcal {L}_{1}+\mathcal {L}_{2}\). Then
and so from (5) we have
where \(R^{\epsilon }\) has the terminal condition
Then, from the Feynman-Kac theorem (probabilistic representation), we have
Here, the first term of the right hand side is convergent in the sense that
where \(b_{1}^{*}\) and \(b_{2}^{*}\) are given by
respectively, and
for some bounded function \(C_{1}\). Here, all the moments of \(Y_{T}\) with respect to invariant distribution of \(Y_{t}\) are assumed to be well-defined. Hence, there is a bounded function \(C_{2}\left( t,y,z\right) \) independent of \(\epsilon \) such that
Consequently, \(\left| R^{\epsilon }\left( t,y,z\right) \right| \le C_{3}\left( t,y,z\right) \epsilon ^{2}\) for some bounded function \(C_{3}\left( t,y,z\right) \) independent of \(\epsilon \) and thus
for some bounded function \(C\left( t,y,z\right) \) independent of \(\epsilon \).
Remark
The invariant distributions \(\phi ^*_z\) of the mean-reverting process \(Y_t\) given \(Z_{t}=z\) for various \(\alpha \) are as follows.
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\(\alpha =1\):
$$\begin{aligned} \phi ^*_z\left( y\right) =\frac{\zeta ^{\eta }}{\Gamma \left( \eta \right) } \frac{e^{-\zeta /y}}{y^{1+\eta }}, \end{aligned}$$which is a density of the inverse gamma distribution with shape parameter \(\eta =1+1/\nu ^{2}\) and scale parameter \(\zeta =z/\nu ^{2}\).
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\(\alpha =\frac{1}{2}\):
$$\begin{aligned} \phi ^*_z\left( y\right) =\frac{1}{\nu ^{2\theta }\Gamma \left( \theta \right) } y^{\theta -1}e^{-y/\nu ^{2}}, \end{aligned}$$which is a density of the gamma distribution with shape parameter \(\theta =z/\nu ^{2}\) and scale parameter \(\nu ^{2}\).
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\(\frac{1}{2}<\alpha <1\):
$$\begin{aligned} \phi ^*_z\left( y\right) =\frac{1}{Cy^{2\alpha }}\mathrm{exp}\left( \frac{z}{\nu ^{2}\left( 1-2\alpha \right) }y^{1-2\alpha }-\frac{1}{\nu ^{2}\left( 2-2\alpha \right) }y^{2-2\alpha }\right) , \end{aligned}$$where C is a constant such that \(\int _{0}^{\infty }\phi ^*_z=1\) holds.
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Huh, J., Jeon, J. & Kim, JH. A scaled version of the double-mean-reverting model for VIX derivatives. Math Finan Econ 12, 495–515 (2018). https://doi.org/10.1007/s11579-018-0213-8
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DOI: https://doi.org/10.1007/s11579-018-0213-8