Estimation, Evaluation, and Selection of Actuarial Models
Estimation, Evaluation, and Selection of Actuarial Models Estimation, Evaluation, and Selection of Actuarial Models
118 APPENDIX A. SOLUTIONS TO EXERCISES The first two second partial derivatives do not contain x j and so the expected value is equal to the indicated quantity. For the final second partial derivative, E( ¯X) =E(X) =αθ. Therefore, " # n Γ(α)Γ00 (α)−Γ 0 (α) 2 I(α, θ) = Γ(α) nθ −1 2 nθ −1 nαθ −2 . The derivatives of the gamma function are available in some better computer packages, but are not available in Excel. Using numerical derivatives of the gamma function yields · ¸ I(ˆα, ˆθ) 82.467 0.0078091 = 0.0078091 0.0000016958 and the covariance matrix is · 0.021503 −99.0188 −99.0188 1, 045, 668 Numerical second derivatives of the likelihood function (using h 1 =0.00005 and h 2 =0.25) yield · ¸ · ¸ I(ˆα, ˆθ) 82.467 0.0078091 0.021502 −99.0143 = and covariance matrix . 0.0078091 0.0000016959 −99.0143 1, 045, 620 The confidence interval for α is 0.55616 ± 1.96(0.021502) 1/2 or 0.55616 ± 0.28741 and for θ is 2561.1 ± 1.96(1, 045, 620) 1/2 or 2561.1 ± 2004.2. Exercise 68 The density function is f(x|θ) =θ −1 , 0 ≤ x ≤ θ. The likelihood function is ¸ . L(θ) = θ −n , 0 ≤ x 1 ,...,x n ≤ θ = 0, otherwise. As a function of θ, the likelihood function is sometimes 0, and sometimes θ −n . In particular, it is θ −n only when θ isgreaterthanorequaltoallthexs. Equivalently, we have L(θ) = 0, θ < max(x 1 ,...,x n ) = θ −n , θ ≥ max(x 1 ,...,x n ). Therefore, the likelihood function is maximized at ˆθ =max(x 1 ,...,x n ). Note that the calculus technique of setting the derivative equal to zero does not work here because the likelihood function is not continuous (and therefore not differentiable) at the maximum. From Examples 3.7 and 3.10 we know that this estimator is asymptotically unbiased and consistent and we have its variance without recourse to Theorem 3.29. According to Theorem 3.29, we need l(θ) = −n ln θ, θ ≥ max(x 1 ,...,x n ) l 0 (θ) = −nθ −1 , θ ≥ max(x 1 ,...,x n ) l 00 (θ) = nθ −2 , θ ≥ max(x 1 ,...,x n ). Then E[l 00 (θ)] = nθ −2 because with regard to the random variables, nθ −2 is a constant and therefore its expected value is itself. The information is then the negative of this number and must be negative.
119 With regard to assumption (ii) of Theorem 3.29, Z θ 0 Z ∂ 1 θ ∂θ θ dx = −θ −2 dx = − 1 0 θ 6=0. Exercise 69 From Exercise 67 we have ˆα =0.55616, ˆθ =2, 561.1 and covariance matrix · ¸ 0.021503 −99.0188 . −99.0188 1, 045, 668 The function to be estimated is g(α, θ) =αθ with partial derivatives of θ and α. The approximated variance is £ ¤ · ¸· ¸ 0.021503 −99.0188 2, 561.1 2, 561.1 0.55616 = 182, 402. −99.0188 1, 045, 668 0.55616 The confidence interval is 1, 424.4 ± 1.96 √ 182, 402 or 1, 424.4 ± 837.1. Exercise 70 The partial derivatives of the mean are ∂e µ+σ2 /2 ∂µ ∂e µ+σ2 /2 = e µ+σ2 /2 = 123.017 = σe µ+σ2 /2 =134.458. ∂σ The estimated variance is then £ ¤ · ¸· ¸ 0.1195 0 123.017 123.017 134.458 = 2887.73. 0 0.0597 134.458 Exercise 71 The first partial derivatives are ∂l(α, β) ∂α ∂l(α, β) ∂β = −5α − 3β +50 = −3α − 2β +2. The second partial derivatives are ∂ 2 l(α, β) ∂α 2 = −5 ∂ 2 l(α, β) ∂β 2 = −2 ∂ 2 l(α, β) ∂α∂β = −3 and so the information matrix is · 5 3 3 2 ¸ .
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118 APPENDIX A. SOLUTIONS TO EXERCISES<br />
The first two second partial derivatives do not contain x j <strong>and</strong> so the expected value is equal to the<br />
indicated quantity. For the final second partial derivative, E( ¯X) =E(X) =αθ. Therefore,<br />
"<br />
#<br />
n Γ(α)Γ00 (α)−Γ 0 (α) 2<br />
I(α, θ) =<br />
Γ(α)<br />
nθ −1<br />
2<br />
nθ −1 nαθ −2 .<br />
The derivatives <strong>of</strong> the gamma function are available in some better computer packages, but are not<br />
available in Excel. Using numerical derivatives <strong>of</strong> the gamma function yields<br />
· ¸<br />
I(ˆα, ˆθ) 82.467 0.0078091<br />
=<br />
0.0078091 0.0000016958<br />
<strong>and</strong> the covariance matrix is · 0.021503 −99.0188<br />
−99.0188 1, 045, 668<br />
Numerical second derivatives <strong>of</strong> the likelihood function (using h 1 =0.00005 <strong>and</strong> h 2 =0.25) yield<br />
· ¸<br />
· ¸<br />
I(ˆα, ˆθ) 82.467 0.0078091<br />
0.021502 −99.0143<br />
=<br />
<strong>and</strong> covariance matrix<br />
.<br />
0.0078091 0.0000016959<br />
−99.0143 1, 045, 620<br />
The confidence interval for α is 0.55616 ± 1.96(0.021502) 1/2 or 0.55616 ± 0.28741 <strong>and</strong> for θ is<br />
2561.1 ± 1.96(1, 045, 620) 1/2 or 2561.1 ± 2004.2.<br />
Exercise 68 The density function is f(x|θ) =θ −1 , 0 ≤ x ≤ θ. The likelihood function is<br />
¸<br />
.<br />
L(θ) = θ −n , 0 ≤ x 1 ,...,x n ≤ θ<br />
= 0, otherwise.<br />
As a function <strong>of</strong> θ, the likelihood function is sometimes 0, <strong>and</strong> sometimes θ −n . In particular, it is<br />
θ −n only when θ isgreaterthanorequaltoallthexs. Equivalently, we have<br />
L(θ) = 0, θ < max(x 1 ,...,x n )<br />
= θ −n , θ ≥ max(x 1 ,...,x n ).<br />
Therefore, the likelihood function is maximized at ˆθ =max(x 1 ,...,x n ). Note that the calculus<br />
technique <strong>of</strong> setting the derivative equal to zero does not work here because the likelihood function<br />
is not continuous (<strong>and</strong> therefore not differentiable) at the maximum. From Examples 3.7 <strong>and</strong> 3.10<br />
we know that this estimator is asymptotically unbiased <strong>and</strong> consistent <strong>and</strong> we have its variance<br />
without recourse to Theorem 3.29. According to Theorem 3.29, we need<br />
l(θ) = −n ln θ, θ ≥ max(x 1 ,...,x n )<br />
l 0 (θ) = −nθ −1 , θ ≥ max(x 1 ,...,x n )<br />
l 00 (θ) = nθ −2 , θ ≥ max(x 1 ,...,x n ).<br />
Then E[l 00 (θ)] = nθ −2 because with regard to the r<strong>and</strong>om variables, nθ −2 is a constant <strong>and</strong> therefore<br />
its expected value is itself. The information is then the negative <strong>of</strong> this number <strong>and</strong> must be<br />
negative.