Mälardalen University

Transcription

1 Mälardalen University 1/38 Value at Risk and its estimation Anatoliy A. Malyarenko Department of Mathematics & Physics Mälardalen University SE Västerås,Sweden

2 Definition Let S(t) denotes the market value of some portfolio. The Value at Risk (VaR) of that portfolio at a given time horizon t and confidence level p is the loss in market value over the time horizon t that is exceeded with probability 1 p, i.e. 2/38 P{S(t) S(0) < VAR} = 1 p. The Derivative Policy Group has proposed a standard that would set a time horizon t of two weeks and a confidence level p = Statistically speaking, this value at risk measure is the 0.01 critical value of the probability distribution of changes in market value.

3 3/38 Figure 1: Value at Risk (DPG Standard)

4 4/38 Figure 2: Simple VaR-calculator

5 Different approaches Traditional. Identifying events and causes and linking them statistically using actuarial-based methods. 5/38

6 Different approaches Traditional. Identifying events and causes and linking them statistically using actuarial-based methods. 5/38 Algorithmics. To model losses caused by rare events and unexpected failures in systems, people and environmental factors.

7 A recipe for estimating of VaR 1. Build a model for simulating changes in prices across all underlying markets over the VaR time horizon. 6/38

8 A recipe for estimating of VaR 1. Build a model for simulating changes in prices across all underlying markets over the VaR time horizon. 6/38 2. Build a data base of portfolio positions. Estimate the size of the current position in each instrument.

9 A recipe for estimating of VaR 1. Build a model for simulating changes in prices across all underlying markets over the VaR time horizon. 6/38 2. Build a data base of portfolio positions. Estimate the size of the current position in each instrument. 3. Develop a model for the revaluation of each derivative for given changes in the underlying market prices and volatilities.

10 A recipe for estimating of VaR 1. Build a model for simulating changes in prices across all underlying markets over the VaR time horizon. 6/38 2. Build a data base of portfolio positions. Estimate the size of the current position in each instrument. 3. Develop a model for the revaluation of each derivative for given changes in the underlying market prices and volatilities. 4. Simulate the change in market value of the portfolio, for each scenario of the underlying market returns. Generate a sufficient number of scenarios to estimate VaR with the desired level of accuracy.

11 Example There are 418 underlying assets covered by RiskMetrics on July 29, A portfolio of plain-vanilla options on these assets is simulated by Monte Carlo: 7/38 Independently, any option is a European call with probability 0.5 and European put with the same probability. Independently, the time to expiration is 1 month with probability 0.4, 3 months with probability 0.3, 6 months with probability 0.2 and 1 year with probability 0.1. Independently, the ratio of exercise price to forward price is lognormally distributed with mean 1. Its logarithm has standard deviation 0.1.

12 Methods for estimating the VaR 1. Actual. Monte Carlo simulation of all underlying asset prices and computation of each option price for each scenario by an exact formula. 8/38 2. Delta. Monte Carlo simulation of all underlying asset prices and approximation of each option price for each scenario by a deltaapproximation of its change in value. 3. Gamma. Monte Carlo simulation of all underlying asset prices and approximation of each option price for each scenario by the delta-gamma approximation Y(, Γ) of its change in value. 4. Analytical-Gamma. The approximation c(p) Var(Y(, Γ)), where c(p) is the p-critical value of the standard normal density.

13 9/38 Figure 3: Value at Risk of long option portfolio plain-vanilla model

14 10/38 Figure 4: Value at Risk of long option portfolio plain-vanilla model

15 Correlated jumps Consider the so called jump-diffusion model 3, in that half of the variance of the annual return of each asset is associated with a jump, with an expected arrival rate of 1 jump per year. We have a more dramatic comparison of different methods. 11/38

16 12/38 Figure 5: Value at Risk for short option portfolio jump-diffusion model

17 13/38 Figure 6: Value at Risk for short option portfolio jump-diffusion model

18 The basic model of return risk Let R t denotes the return of some underlying asset at day t. Then 14/38 R t+1 = µ t + σ t ε t+1, where E{ε t+1 /F t } = 0, Var{ε t+1 /F t } = 1. µ t = E{R t+1 /F t }, σ 2 t = Var{R t+1 /F t }, A model is called plain-vanilla if µ and σ are constant parameters, and ε t are independent standard normal random variables (white noise). Experience shows that in practice distribution of tails is heavy.

19 Jump-diffusion model R t = R 0 exp{αt + X t ), X t = βw t + N(t) k=0 νz k, where W t is a standard Wiener process and N(t) is the number of jumps that occur by time t. This is Poisson process with intensity λ. All jumps νz k are independent and normally distributed with mean zero and standard deviation ν. 15/38

20 16/38 Figure 7: 2-Week 99%-VAR for underlying asset, one jump per year

21 17/38 Figure 8: 2-Week 99%-VAR for underlying asset, two jumps per year

22 Stochastic volatility We will consider only Markovian models of the form 18/38 σ t = F(σ t 1, z t, t), where z t is white noise. In the model of regime-switching volatility, volatility behaves according to a finite-state Markov chain. A model on Fig. 9 illustrates persistence, i.e., relatively high (low) recent volatility implies a relatively high (low) forecast of volatility in the near future. The model of log-auto-regressive volatility is given by log σ 2 t = α + γ log σ 2 t 1 + κz t, where α, γ and κ are constants. A value of γ near 0 implies low persistence, while a value near 1 implies high persistence.

23 19/38 Figure 9: Regime-switching volatility estimates for light crude oil

24 The GARCH (General AutoRegressive Conditional Heteroscedasticity) model assumes that σ 2 t = α + β(r t µ) 2 + γσ 2 t 1. For example, estimated GARCH parameters associated with crude oil have maximum likelihood estimates given by 20/38 α = 0.155, β = 0.292, γ = The cross-market inference can be accounted by the multivariate GARCH model, for example σ 2 a,t σ 2 ab,t σ 2 b,t R 2 a,t = α + β R a,t R b,t R 2 + γ b,t σ 2 a,t 1 σ 2 ab,t 1 σ 2 b,t 1.

25 21/38 Figure 10: Term structure of kurtosis for the jump-diffusion model

26 22/38 Figure 11: Term structure of 0.99 critical value of the jump-diffusion model

27 23/38 Figure 12: Term structure of volatility (Hang Seng Index estimated)

28 24/38 Figure 13: Long-run kurtosis of stochastic volatility model

29 25/38 Figure 14: Estimated term structure of kurtosis for stochastic volatility

30 Estimating current volatility The historical volatility for returns R t, r t+1,..., R T is the usual estimate ˆσ 2 = 1 T (R t,t s ˆµ t,t ), T t where s=t+1 ˆµ t,t = R t R T. T t The constant volatility model can not be applied to essentially every major market, as shown on Fig. 15. The Black Scholes implied volatility σ = σ BS (C t, P t, τ, K, r) is calculated numerically. 26/38

31 27/38 Figure 15: Rolling volatility for Taiwan equity index.

32 VaR calculations for derivatives The delta approximation: 28/38 f(y + x) = f(y) + f (y)x + o(x). The delta-gamma approximation: f(y + x) = f(y) + f (y)x f (y)x 2 + o(x 2 ).

33 29/38 Figure 16: The delta (first-order) approximation

34 30/38 Figure 17: Delta-gamma hedging, second order approximation

35 31/38 Figure 18: 2-Week loss on 20% out-of-money put (plain-vanilla returns)

36 32/38 Figure 19: 2-Week loss on short 20% out-of-money put (plain-vanilla re-

37 33/38 Figure 20: 2-Week loss on short 20% out-of-money put (jump-diffusion)

38 Portfolio VaR Let X i denotes the difference between the i-th risk factor and its expected value. The total change in value for the entire book has the delta-gamma approximation: n Y(, Γ) = j X j + 1 n n Γ jk X j X k. 2 j=1 The portfolio variance is equal to Var(Y(, Γ)) = j k Cov(X j, X k ) + j Γ jk Cov(X i, X j X k ) Back to methods j,k i, j,k,l j=1 k=1 i, j,k Γ i j Γ kl Cov(X i X j, X k X l ). 34/38

39 Simulating fat tailed distributions Suppose one wants to simulate a random variable X of zero mean and unit variance with a given kurtosis. Let η be the Bernoully random variable: P{η = 1} = p, P{η = 0} = 1 p. Let Z be the standard normal random variable independent on η. Define X as αz, η = 1, X = βz, η = 0. Then we have Var(X) = pα 2 + (1 p)β 2, E(X 4 ) = 3(pα 4 + (1 p)β 4 ). Now we can choose α, β and p. 35/38

40 How many scenarios is enough? Let ξ 1, ξ 2,..., be an independently and identically distributed sequence of random variables with E(ξ i ) = µ. Let 36/38 ˆµ(k) = ξ ξ k. k Let g(θ) denotes the moment-generating function of ξ i, that is g(θ) = E[exp(θξ i )]. According to the large deviations theorem, under mild regularity conditions P{ ˆµ(k) δ} e kγ(θ), where γ(θ) = δθ log[g(θ)].

41 Let In our application we let 1, X i > VAR, ξ i = 0, X i VAR. ˆp(k) = ξ ξ k k be the estimate of p. Maximising γ(θ) with respect to θ, we have 37/38 P{ ˆp(k) δ} exp( kγ), where Γ = δ log δ + (1 δ) log(1 δ) δ log p (1 δ) log(1 p). For example, let p = 0.95 and δ = Then Γ = For a confidence of c = 0.99 we see that k = 1 log(c) = 576. Γ

42 Bootstrapped simulation from historical data In a stationary statistical environment no problems. In the case of significant non-stationarity, we update the historical asset distribution. For example, 38/38 ˆR i = R i ˆV V, where V is the historical volatility and ˆV is a recent volatility estimate, or ˆR t = Ĉ 1/2 C 1/2 R t, where R t denotes the vector of historical returns, C denotes the historical covariance matrix for returns across a group of assets under consideration, Ĉ denotes the updated estimate.