Etude des marchés d'assurance non-vie à l'aide d'équilibres de ...
Etude des marchés d'assurance non-vie à l'aide d'équilibres de ...
Etude des marchés d'assurance non-vie à l'aide d'équilibres de ...
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tel-00703797, version 2 - 7 Jun 2012<br />
Chapitre 4. Asymptotiques <strong>de</strong> la probabilité <strong>de</strong> ruine<br />
P(X>x) - log scale<br />
1e-07 1e-05 1e-03 1e-01<br />
Survival function - exp mixing<br />
1 10 100 1000 10000<br />
x - log scale<br />
(a) Exponential<br />
exact<br />
asympto<br />
P(X>x) - log scale<br />
1e-10 1e-08 1e-06 1e-04 1e-02<br />
Survival function - gamma mixing<br />
2 5 10 20 50 200 500 2000<br />
x - log scale<br />
(b) Gamma<br />
asympto<br />
exact<br />
Figure 4.1: Survival functions<br />
P(X>x) - log scale<br />
0.15 0.20 0.25 0.30<br />
Survival function - stable mixing<br />
5 10 50 500 5000<br />
x - log scale<br />
(c) Lévy stable<br />
then, they have a <strong>de</strong>pen<strong>de</strong>nce structure due to an Archime<strong>de</strong>an survival copula with generator<br />
, the inverse Laplace transform of Θ.<br />
φ = L −1<br />
Θ<br />
Therefore, in continuous time, the <strong>de</strong>pen<strong>de</strong>nce structure is simply an Archime<strong>de</strong>an copula.<br />
Regarding the discrete-time setting, things are more complicated: the <strong>de</strong>pen<strong>de</strong>nce among<br />
discrete random variables is a complex topic. Genest and Neslehova (2007) present issues<br />
linked to discrete copula. To better un<strong>de</strong>rstand the problem, we recall the Sklar theorem, see,<br />
e.g., Joe (1997); Nelsen (2006).<br />
Theorem (Sklar). Let H be the bivariate distribution function of a random pair (X, Y ). There<br />
exists a copula C such that for all x, y ∈ R,<br />
exact<br />
asympto<br />
H(x, y) = C(FX(x), FY (y)). (4.9)<br />
Furthermore, C is unique on the Cartesian product of the ranges of the marginal distributions.<br />
As a consequence, the copula C is not unique outsi<strong>de</strong> the support of the random variables<br />
X and Y . When X, Y are discrete variables in N, C is only unique on N 2 but not on R 2 \ N 2 .<br />
The <strong>non</strong>-i<strong>de</strong>ntifiability is a major source of issues. An example of discrete copulas is the<br />
empirical copula for observation sample (Xi, Yi)1≤i≤n.<br />
Some problems in the discrete case arise from the discontinuity of the distribution function<br />
of discrete random variables. Let B be a Bernoulli variable B(p). The distribution function<br />
FB, given by FB(x) = (1 − p) 1x≥0 + p 1x≥1, is discontinuous. Thus, the random variable<br />
FB(B) is not a uniform variable U(0, 1).<br />
Let us introduce Genest and Neslehova (2007)’s notation. Let A be the class of functions<br />
verifying Equation (4.9) for all x, y ∈ R for a given FX and FY . Let us <strong>de</strong>fine the function<br />
B as for all u, v ∈ [0, 1], B(u, v) = (F −1 −1<br />
X (u), FY (v)). We also <strong>de</strong>note by D the distribution<br />
function of the pair (FX(X), FY (Y )).<br />
With a simple bivariate Bernoulli vector, Example 1 of Genest and Neslehova (2007) shows<br />
that (i) functions B and D are different, (ii) B is not a distribution function <strong><strong>de</strong>s</strong>pite both B<br />
and D belong to the class A. Even in that simple support {0, 1} 2 , the i<strong>de</strong>ntifiability issue of<br />
the copula C cannot be discar<strong>de</strong>d. Proposition 1 of Genest and Neslehova (2007) extends to<br />
196