tel-00703797, version 2 - 7 Jun 2012 Chapitre 4. Asymptotiques <strong>de</strong> la probabilité <strong>de</strong> ruine Getting back the original <strong>de</strong>finition, we have ∆i,0 = P (W1 ≤ i, W2 ≤ 0) = P (W1 ≤ i, W2 ≤ 0) = 1 − LΘ(i + 1) − LΘ(1) + LΘ(i + 2). Since LΘ is convex, the sequence LΘ(i + 2) − LΘ(i + 1) is an increasing sequence. We conclu<strong>de</strong> that (∆i,1)i is increasing, so the maximum is attained at +∞. Therefore, max i,j ∆i,j = ∆+∞,0 = P (W1 ≤ +∞, W2 ≤ 0) = P (W2 = 0). On Figure 4.2, we investigate the numerical differences with a given distribution for the latent variable. We consi<strong>de</strong>r Θ follows a gamma distribution Ga(2, 4). In other words, we assume α λ LΘ(t) = ⇔ L λ + t −1 Θ (z) = λ(z−1/α − 1), with α = 2, λ = 4. We plot the unique continuous copula CY1,Y2 and the distribution function , left-hand and right-hand graphs, respectively. DW1,W2 1.0 0.8 C(u,v) 0.6 0.4 0.2 Continuous case - Gamma G(2,4) 0.0 0.0 0.2 0.4 u 0.6 0.8 1.00.0 0.2 (a) Continuous case 0.4 0.6 v 1.0 0.8 Figure 4.2: Comparison of copula CY1,Y2 1.0 0.8 H(u,v) 0.6 0.4 0.2 Discrete case - Gamma G(2,4) 0.0 0.0 0.2 0.4 u 0.6 0.8 1.00.0 (b) Discrete case 0.2 0.4 0.6 v 1.0 0.8 and distribution function DW1,W2 CY1,Y2 passes through all the top-left corners of the stairs <strong><strong>de</strong>s</strong>cribed by HW1,W2 . The grid of points used for the graphs is {(FW1 (n), FW2 (m)), n, m ∈ N}. As n increases, the distribution function FW1 (n) tends 1, so there infinitely many stairs towards the point (1, 1). Graphically, the maximal stairstep corresponds to (u, v) = (1, FW2 (0)) or (FW1 (0), 1) and ∆∞,0 = 0.36. The maximal stairstep is also the maximum difference between copula CY1,Y2 and distribution function DW1,W2 . 4.4.3 Non-i<strong>de</strong>ntifiability issues The function DW1,W2 is not a copula but only a distribution function. The maximal stairstep leads to the question of the maximal differences between two copulas satisfying 200
tel-00703797, version 2 - 7 Jun 2012 Equation (4.9) H(x, y) = C(FX(x), FY (y)), 4.4. Focus on the <strong>de</strong>pen<strong>de</strong>nce structure when X, Y take discrete values. The answer is given by the Carley bounds C − H , C+ H . For all copulas CH verifying Equation (4.9), we have C − H ≤ CH ≤ C + H , cf. Proposition 2 of Genest and Neslehova (2007). The <strong>non</strong>-i<strong>de</strong>ntifiability issue matters, since with discrete copulas the <strong>de</strong>pen<strong>de</strong>nce measure, such as the tau of Kendall or the rho of Spearman, are no longer unique. Furthermore, if X and Y are in<strong>de</strong>pen<strong>de</strong>nt, it does not imply that the copula of (X, Y ) is the in<strong>de</strong>pen<strong>de</strong>nt copula. In other words, the copula alone does not characterize the <strong>de</strong>pen<strong>de</strong>nce: we need assumptions on margins. In the copula literature, efforts have been done to tackle the <strong>non</strong>-i<strong>de</strong>ntifiability issue of <strong>de</strong>pen<strong>de</strong>nce measure. The current answer is the interpolated copula C X,Y , which is a bilinear interpolation of the distribution function D of the pair (F (X), F (Y )) on the discrete set Im(FX) × Im(FY ). Let (ui, vj) ∈ Im(FX) × Im(FY ), i.e. ui = FX(i) and uj = FX(j). For all (u, v) ∈ [ui, ui+1] × [vj, vj+1], the interpolated copula is <strong>de</strong>fined as C X,Y (u, v) = ¯ λu ¯ λvD(ui, vj)+λu ¯ λvD(ui+1, vj)+ ¯ λuλvD(ui, vj+1)+λuλvD(ui+1, vj+1), (4.12) where λu = (u−ui)/(ui+1 −ui), λv = (v −vj)/(vj+1 −vj). This copula was already mentioned in Lemma 2.3.5 of Nelsen (2006) to prove the Sklar theorem. The interpolated copula can also be interpreted as the copula of (X + U, Y + V ) where U, V are two in<strong>de</strong>pen<strong>de</strong>nt uniform random variables, see, e.g., Section 4 of Denuit and Lambert (2005). This formulation is useful when doing random generation. The properties of the interpolated copula of the pair (X, Y ) are: (i) Kendall’s tau τ(X, Y ) = τ(C X,Y ) and Spearman’s rho ρ(X, Y ) = ρ(C X,Y ), (ii) C X,Y is absolutely continuous and (iii) <strong>de</strong>pends on marginals X ⊥ Y ⇔ C X,Y = Π, the in<strong>de</strong>pen<strong>de</strong>nt copula. Unfortunately, C X,Y and when FX = FY does not imply C X,Y (u, v) = min(u, v), as well as FX = 1 − FY C X,Y (u, v) = (u + v − 1)+, see, e.g., Genest and Neslehova (2007). As the interpolated copula is absolutely continuous, a <strong>de</strong>nsity can be <strong>de</strong>rived. In<strong>de</strong>ed, by differentiating Equation (4.12) with respect to u and v, we get c X,Y (u, v) = D(ui, vj) − D(ui+1, vj) − D(ui, vj+1) + D(ui+1, vj+1) , (4.13) (ui+1 − ui)(vj+1 − vj) for (u, v) ∈ [ui, ui+1] × [vj, vj+1]. To better see the differences between the copula CY1,Y2 and the interpolated copula C W1,W2 , we choose to plot the <strong>de</strong>nsities on Figure 4.3 and not the distribution functions. On Figure 4.3, we plot <strong>de</strong>nsities of the continuous copula of the pair (Y1, Y2) and the interpolated copula of the pair (W1, W2), in the same setting as the previous subsection, i.e. Θ is gamma distributed Ga(2, 4). 4.4.4 Zero-modified distributions In the previous Subsections, we worked only with a simple geometric distribution. Following the mo<strong>de</strong>l presented in Subsection 4.2.2, we use hereafter a zero-modified distribution 201
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