Does Tail Dependence Make A Difference In the ... - Boston College
Does Tail Dependence Make A Difference In the ... - Boston College
Does Tail Dependence Make A Difference In the ... - Boston College
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Theorem 1 (Sklar)(1959) Let G be a joint distribution function with n marginals F i .<br />
exists an n dimension copula C such that<br />
(<br />
)<br />
G(x 1 , x 2 , · · · , x n ) = C F 1 (x 1 ), F 2 (x 2 ), · · · , F n (x n )<br />
Then <strong>the</strong>re<br />
If all margins F i are continuous, <strong>the</strong>n <strong>the</strong> copula C is unique.<br />
<strong>In</strong> contrast to <strong>the</strong> traditional dependence measure like Pearson’s correlation ρ and Kendall’s τ, <strong>the</strong> copula model<br />
is capable of measuring <strong>the</strong> whole dependence structure including tail dependence between random variates.<br />
Definition 1: <strong>Tail</strong> <strong>Dependence</strong><br />
Let X 1 and X 2 be two random variables with CDF F 1 and F 2 . Then <strong>the</strong> lower tail dependence (LTD)<br />
coefficient of two random variables (X 1 , X 2 ) is defined as<br />
LT D(X 1 , X 2 ) =<br />
(<br />
)<br />
lim Pr X 2 < F −1<br />
u−→0 + 2 (u)|X 1 < F1 −1<br />
C(u, u)<br />
(u) = lim<br />
u−→0 + u<br />
Analogously, <strong>the</strong> upper tail dependence (UTD) coefficient of two random variables (X 1 , X 2 ) is defined<br />
as<br />
(<br />
)<br />
UT D(X 1 , X 2 ) = lim Pr X 2 > F −1<br />
u−→1 − 2 (u)|X 1 > F1 −1<br />
1 − 2u + C(u, u)<br />
(u) = lim<br />
u−→1 − 1 − u<br />
<strong>In</strong> <strong>the</strong> following, a wide range of copula models are to be used to estimate <strong>the</strong> systemic risk measures ∆CoV aR<br />
and MES, and we will study <strong>the</strong>ir relationship with <strong>the</strong> tail dependence between <strong>the</strong> financial institutions and<br />
market.<br />
2.2.1 ∆ CoVaR Estimation<br />
If <strong>the</strong> joint distribution F (x, y) has a continuous marginal distribution, Sklar’s Theorem (1959) stated that<br />
<strong>the</strong>re exists a unique copula function such that any bivariate distribution can be represented by <strong>the</strong> combination<br />
of <strong>the</strong>ir marginal distributions in a certain form of copula function:<br />
(<br />
)<br />
F (x, y) = C F x (x), F y (y); θ = C(u, v; θ)<br />
where u and v are <strong>the</strong> marginal distributions F x (x) and F y (y) of x and y respectively. Differentiating C(u, v; θ)<br />
with respect to u, we can obtain <strong>the</strong> conditional distribution of y given x (See <strong>the</strong> proof in <strong>the</strong> Appendix):<br />
F (y|x) =<br />
∂C(u, v; θ)<br />
∂u<br />
= C 1 (u, v; θ) = C 1 (F x (x), F y (y); θ)<br />
where F (y|x) denotes <strong>the</strong> conditional distribution of y given x and C 1 (u, v; θ) represents <strong>the</strong> partial derivative of<br />
<strong>the</strong> copula with respect to <strong>the</strong> first argument.<br />
By defining τ = F (y|x) and inverting C 1 with respect to <strong>the</strong> second argument can derive <strong>the</strong> marginal distribution<br />
of y: F y (y) as<br />
F y (y) = C −1<br />
1 (F x(x), τ; θ)<br />
Let x = V aR x (τ), and y = CoV aRτ<br />
y|x . The solution for CoVaR in <strong>the</strong> context of <strong>the</strong> copula framework can be<br />
explicitly expressed as:<br />
( (<br />
CoVaR y|x<br />
τ<br />
= F −1<br />
y<br />
C −1<br />
1<br />
9<br />
F x (V aR x (τ)), τ, θ) ) (1)