Contents
Cover
Half Title page
Title page
Copyright page
Preface
Chapter 1: Introduction
Chapter 2: Coxian and Related Distributions
2.1 Introduction
2.2 Combinations of Exponentials
2.3 Coxian-2 Distributions
Chapter 3: Mixed Erlang Distributions
3.1 Introduction
3.2 Members of the Mixed Erlang Class
3.3 Distributional Properties
3.4 Mixed Erlang Claim Severity Models
Chapter 4: Extreme Value Distributions
4.1 Introduction
4.2 Distribution of the Maximum
4.3 Stability of the Maximum of the Extreme Value Distribution
4.4 The Fisher–Tippett theorem
4.5 Maximum Domain of Attraction
4.6 Generalized Pareto Distributions
4.7 Stability of Excesses of the Generalized Pareto
4.8 Limiting Distributions of Excesses
4.9 Parameter Estimation
Chapter 5: Analytic and Related Methods for Aggregate Claim Models
5.1 Introduction
5.2 Elementary Approaches
5.3 Discrete Analogues
5.4 Right-Tail Asymptotics for Aggregate Losses
Chapter 6: Computational Methods for Aggregate Models
6.1 Recursive Techniques for Compound Distributions
6.2 Inversion Methods
6.3 Calculations with Approximate Distributions
6.4 Comparison of Methods
6.5 The Individual Risk Model
Chapter 7: Counting Processes
7.1 Nonhomogeneous Birth Processes
7.2 Mixed Poisson Processes
Chapter 8: Discrete Claim Count Models
8.1 Unification of the (a, b, 1) and Mixed Poisson Classes
8.2 A Class of Discrete Generalized Tail-Based Distributions
8.3 Higher Order Generalized Tail-Based Distributions
8.4 Mixed Poisson Properties of Generalized Tail-Based Distributions
8.5 Compound Geometric Properties of Generalized Tail-Based Distributions
Chapter 9: Compound Distributions with Time Dependent Claim Amounts
9.1 Introduction
9.2 A Model for Inflation
9.3 A Model for Claim Payment Delays
Chapter 10: Copula Models
10.1 Introduction
10.2 Sklar’s Theorem and Copulas
10.3 Measures of Dependency
10.4 Tail Dependence
10.5 Archimedean Copulas
10.6 Elliptical Copulas
10.7 Extreme Value Copulas
10.8 Archimax Copulas
10.9 Estimation of Parameters
10.10 Simulation from Copula Models
Chapter 11: Continuous-Time Ruin Models
11.1 Introduction
11.2 The Adjustment Coefficient and Lundberg’s Inequality
11.3 An Integrodifferential Equation
11.4 The Maximum Aggregate Loss
11.5 Cramer’s Asymptotic Ruin Formula and Tijms’ Approximation
11.6 The Brownian Motion Risk Process
11.7 Brownian Motion and the Probability of Ruin
Chapter 12: Interpolation and Smoothing
12.1 Introduction
12.2 Interpolation with Splines
12.3 Extrapolating with Splines
12.4 Smoothing with Splines
Appendix A: An Inventory of Continuous Distributions
A.1 Introduction
A.2 Transformed Beta Family
A.3 Transformed Gamma Family
A.4 Distributions for Large Losses
A.5 Other Distributions
A.6 Distributions with Finite Support
Appendix B: An Inventory of Discrete Distributions
B.1 Introduction
B.2 The (a, b, 0) Class
B.3 The (a, b, 1) Class
B.4 The Compound Class
B.5 A Hierarchy of Discrete Distributions
Appendix C: Discretization of the Severity Distribution
C.1 The Method of Rounding
C.2 Mean Preserving
C.3 Undiscretization of a Discretized Distribution
Appendix D: Solutions to Exercises
D.1 Chapter 4
D.2 Chapter 5
D.3 Chapter 6
D.4 Chapter 7
D.5 Chapter 8
D.6 Chapter 10
D.7 Chapter 11
D.8 Chapter 12
References
Index
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Library of Congress Cataloging-in-Publication Data:
Klugman, Stuart A., 1949–
Loss models : further topics / Stuart A. Klugman, Society of Actuaries, Schaumburg, IL, Harry H. Panjer,
Department of Statistics and Actuarial Science, University of Waterloo, Ontario, Canada, Gordon E. Willmot,
Department of Statistics and Actuarial Science, University of Waterloo, Ontario, Canada.
pages cm
Includes bibliographical references and index.
ISBN 978-1-118-34356-2 (cloth)
1. Insurance—Statistical methods. 2. Insurance—Mathematical models. I. Panjer, Harry H. II. Willmot, Gordon E.,– III. Title.
HG8781.K584 2013
368’.01—dc23
2013009457
PREFACE
Readers who have been with us since the first edition may have noticed that each edition added several new topics while few were dropped. By the third edition, a limit had been reached and it was time to rethink how the material was presented. With the encouragement of our publisher, we decided to produce two books. The first, published in 2012, is the fourth edition, continuing to be called Loss Models: From Data to Decisions [58]. In that book we included all the topics currently covered on the examinations of the Casualty Actuarial Society and the Society of Actuaries (with some updates to specific topics). We also included a few topics we think may be worth adding in the future (and that we like to teach). When designing this companion book, we wanted to do two things. The first was to cover the topics from the third edition that had been excluded from the fourth edition. These are:
The second was to add new material, particularly with regard to expanding the number of models presented and demonstrating how they apply to actuarial problems. The new topics are (though some include material that was in the third edition):
We have viewed this companion book as more of a practitioner’s and researcher’s resource than a textbook and thus have only created exercises where additional concepts are introduced. However, for material brought over from the third edition, those exercises have been retained. Solutions to all exercises are in an Appendix. Together with the fourth edition, we believe the two books present a comprehensive look at the current state of this aspect of actuarial work. We are thankful for the continued support and encouragement from John Wiley & Sons and the Society of Actuaries. We also thank Joan Hatton for her expert typing and Mirabelle Huynh who did a thorough job of proofreading our writing.
S. A. KLUGMAN, H. H. PANJER, G. E. WILLMOT
Schaumburg, IL and Waterloo, Ontario
As noted in the preface, the purpose of this book is to provide information on topics not covered in the fourth edition of Loss Models: From Data to Decisions [59]. In general, the emphasis here is less on data and decisions and more on what is in between, namely the vast array of models available for actuarial work. In this introduction we give a brief overview of the models covered. The material can be broken up into six sets of topics.
Three chapters are devoted to classes of univariate models. The first is the class of Coxian distributions (Chapter 2). These distributions have the desirable property that their Laplace transform (or, equivalently, their moment generating function) is a ratio of polynomials. Thus, when used as a claim size distribution, convenient explicit expressions for the associated aggregate or compound distribution may sometimes be derived. The second is the class of mixed Erlang distributions (Chapter 3). These distributions are notable because they can approximate any positive continuous distribution to an arbitrary degree of accuracy. Moreover, the mixed Erlang class contains a large number of distributions, including some whose mixed Erlang structure is not obvious. Also, calculations of most quantities of interest in an insurance loss context are computationally straightforward. The third chapter (Chapter 4) covers the two classes of extreme value distributions. This material is largely reproduced from the third edition [58] with some additional material on tail calculations.
As the name implies, these models are especially useful for management of risks that may produce large losses.
The basic methods for these calculations are covered in the fourth edition. This book contains two enhancements. Some of the univariate models introduced in the early chapters allow for exact calculation of aggregate loss probabilities. The formulas are developed in Chapter 5 along with asymptotic formulas for the right tail. Computational methods left out of the fourth edition are provided in Chapter 6. These include inversion methods, calculating with approximate distributions, and calculating from the individual risk model (which was in the second edition, but not the third). A new item is a presentation of the recursive formula when the frequency distribution is a member of the (a, b, m) class of distributions.
The next three chapters focus on various issues that are of interest in the loss modeling context. The first chapter (Chapter 7) introduces counting processes and, as in the third edition, deals with nonhomogeneous birth processes and mixed Poisson processes, which are useful for modeling the development of claim counts over time. Chapter 8 is new and considers properties of discrete counting distributions that are of interest in connection with loss model concepts such as deductibles and limits, recursions for compound distributions, evaluation of stop-loss moments, and computation of the risk measures VaR and TVaR in a discrete setting. The third chapter (Chapter 9) deals with models where the claim amounts depend on the time of incurral of the claim. Examples include inflation and claim payment delays.
Chapter 10 covers the analysis of multivariate models based on copula functions. The material is taken from the third edition. Methods for simulation that were in a later chapter of the third edition were moved to this chapter.
The material in Chapter 11 is taken directly from the third edition. It contains the classic analysis of the infinite-time ruin problem.
While this material was covered in the third edition, two changes have been made for Chapter 12. First, some of the earlier material has been eliminated or streamlined. The goal is to efficiently arrive at the smoothing spline, the method most suitable for actuarial problems. More emphasis is placed on the most common application, the smoothing of data from experience studies. A traditional actuarial method, Whittaker–Henderson, has been added along with discussion of its similarity to smoothing splines.
For the analysis of aggregate claims, the typical models involve compound distributions, which result in analytical complexities. A useful feature of compound distributions is the simplicity of the probability generating function (for discrete cases) and the Laplace transform (for continuous cases). This characteristic can be exploited to obtain useful results from either a mathematical or computational viewpoint. Because the class of Coxian distributions is defined through its Laplace transform, members of the class are well suited for use as claim amount distributions in aggregate claims models. In this chapter we briefly discuss two fairly broad classes of models that have been used in applications involving loss models. Both are subclasses of the class of Coxian distributions, which we now define.
Definition 2.1 A distribution is from the Coxian-n class if its Laplace transform (s) = dx may be expressed as
(2.1)
where λi > 0 for i = 1, 2,…, m and (without loss of generality) we assume that λi ≠ λj for i ≠ j. We further assume that ni is a nonnegative integer for i = 1, 2, …, m and that n = ∑mi=1 ni > 0. Also, a(s) is a polynomial of degree n − 1 or less.
As (0) = 1, it follows that . Furthermore, a partial fraction expansion of (2.1) yields
(2.2)
where
(2.3)
Note that
(2.4)
where
(2.5)
is the probability density function (pdf) of an Erlang-j random variable with scale parameter λi. Then, from (2.2) and also (2.4), the Coxian-n class has pdf of the form
with eλi,j (x) given by (2.5), which is a finite combination of Erlang pdfs. We now discuss the special case when ni = 1 for i = 1, 2,…, m.
Suppose that X has pdf of the form
(2.6)
where λi ≥ 0 for i = 1, 2, …, n. The condition that = 1 implies that ∑ni=1 qi = 1, and if 0 ≤ qi ≤ 1 for i = 1, 2, …, n then (2.6) may be interpreted as a mixture of exponential pdfs.
But (2.6) is a pdf in many cases even if some of the qi are negative, in which case (2.6) may be referred to as a combination (or a generalized mixture) of exponentials. Two examples where this occurs are now given.
Suppose that Xi has the exponential distribution with mean 1/λi for i = 1, 2, …, n, where λi ≠ λj. Let Sn = X1 + ··· + Xn. Then Sn is said to have a generalized Erlang pdf where it is further assumed that X1, X2, …, Xn are independent. Clearly,
which is of the form (2.1) with ni = 1 for i = 1, 2, …, m. Then a partial fraction expansion yields immediately that
(2.7)
Thus, for i = 1, 2, …, n,
and substitution of s = −λi yields
(2.8)
We remark that (2.7) and (2.8) also follow directly from (2.2) and (2.3), respectively. Thus, from (2.7), Sn has pdf
(2.9)
where qi is given by (2.8) and (2.9) is of the form (2.6).
The use of the partial fraction expansion in the previous example is essentially equivalent to Lagrange’s polynomial representation. That is, if x1, x2, …, xn are distinct numbers and g(x) is a polynomial of degree n − 1 or less, then g(x) may be expressed in terms of the functional values g(xi) for i = 1, 2, …, n as
(2.10)
An important special case of (2.10) is when g(x) = 1, yielding the identity
(2.11)
If x = 0 in (2.11) and xj = λj, it follows immediately that ∑ni=1 qi = 1, where qi is given by (2.8), a condition necessary for (2.9) to be a pdf. Also, (2.11) may be viewed as a polynomial identity in x. The left-hand side is a polynomial of degree n − 1 in x, with coefficient of xn−1 satisfying
(2.12)
because the coefficient of xn−1 on the right-hand side of (2.11) is 0. This proves the outer equality in (2.12), and the left-hand equality in (2.12) follows by multiplication by (−1)n−1. It is clear from (2.8) and (2.9) that
and thus (2.12) with xj = λj implies that fSn (0) = 0 if n = 2, 3,….
We now consider a second example of a combination of exponentials.
Suppose that Y has the beta pdf
where α > −1 and n is a positive integer. Now consider the random variable X defined by Y = e−λX, so that X = − ln Y. Thus the cdf of X is
and differentiation yields the pdf
Noting that and applying a binomial expansion to (1 − e−λx)n−1 yield
A change in the index of summation from k to i = k + 1 yields
that is,
(2.13)
where λi = λ(α + i) and
(2.14)
It is useful to note that if i = 1, 2, …, n,
and thus (2.14) may also be expressed as
(2.15)
Now, with xi = −i, (2.10) becomes
implying from (2.15) that g(α) = ∑ni=1 qig(−i) for any polynomial g(x) of degree n − 1 or less. Thus, with g(x) = 1, it follows that ∑ni=1 qi = 1, a condition that again must hold for (2.13) to be a pdf.
The class of combinations of exponentials is an important class of distributions as it is dense in the set of probability distributions on [0, ∞), implying that any such probability distribution may be approximated by a combination of exponentials. Dufresne [19] considers this approximation problem and uses logbeta pdfs of the type considered in Example 2.2 in this context. Interestingly, the terminology “logbeta” is also due to Dufresne [19] and is more appropriate than the use of the term “lognormal” in that the log (not the exponential) of a lognormal random variable is normally distributed.
Assuming without loss of generality that λ1 < λ2 < · · · < λn, necessary conditions for (2.6) to be a valid pdf are that q1 > 0 and ∑ni=1 qiλi ≥ 0, and these conditions are also sufficient if there is not more than one sign change in the sequence {q1,q2, …, qn}, obviously the case if n = 2. See Steutel and van Harn [89, pp. 338–339] for further details. Again assuming that λ1 < λ2 < · · · < λn, Bartholomew [7] shows that alternative sufficient conditions for (2.6) to be a valid pdf are that ∑ki=1 qiλi ≥ 0 for k = 1, 2, …, n.
In the Coxian-n case with n = 2, a(s) is a linear function of s, and thus (2.1) may be expressed as
(2.16)
where λ1 > 0, λ2 > 0, and λ1 = λ2 is possible. We wish to consider values of p for which (2.16) is the Laplace transform of a pdf. First, note that if p = 0 then (s) = λ1/(λ1 + s), which is the Laplace transform of an exponential (with mean 1/λ1) pdf. Similarly, if p = 1 − λ2/λ1, that is, λ2 = λ1 (1 − p), then (s) = λ2/(λ2 + s), again of exponential form. Thus we exclude the cases with p = 0 and p = 1 − λ2/λ1 in what follows.
It is clear from (2.16) that
(2.17)
which implies that
(2.18)
where
(2.19)
Clearly, h(x) is easy to evaluate, but its form depends on whether λ1 = λ2 or not. In any event, h(0) = 0 from (2.19), implying from (2.18) that f(0) = λ1(1 − p), and so the condition p ≤ 1 is required for f(x) to be a valid pdf. The Laplace transform of the tail is, from (2.17),
from which it follows that
Thus, again using (2.19),
(2.20)
If λ1 ≥ λ2 then from (2.19) limx→∞ h(x) = ∞, and thus from (2.20) it is clear that p ≥ 0 because if p < 0 then would become negative for large x. But it was assumed that p ≠ 0, and thus if λ1 ≥ λ2 it follows that 0 < p ≤ 1. Thus if λ1 = λ2 = λ, (2.18) and (2.19) yield
(2.21)
which is the pdf of the mixture of two Erlang pdfs, both with the same scale parameter λ. We remark that pdfs of the form (2.21) will be discussed in much detail later.
If λ1 < λ2 then from (2.19)
and thus from (2.20)
This limit obviously cannot be negative, and it follows that λ2 − λ1 + pλ1 ≥ 0, i.e., p ≥ 1 − λ2/λ1, which is equivalent to λ2 ≥ λ1 (1 − p). But again it is assumed that p ≠ 1 − λ2/λ1, and therefore if λ1 < λ2 then 1 − λ2/λ1 < p ≤ 1 but p ≠ 0.
If λ1 ≠ λ2 then
(2.22)
which follows directly or from (2.7) and (2.8). Substitution of (2.22) into (2.17) yields
That is, if λ1 ≠ λ2,
(2.23)
where
(2.24)
If 0 < p ≤ 1 then (2.23) is either a mixture or a combination of two exponential pdfs. However, if p < 0 then one must have λ1 < λ2, and α > 0 from (2.24). But if p is negative, one must have 1 − λ2/λ1 < p, or equivalently λ1 − λ2 < λ1p, and because λ1 − λ2 must also be negative, 1 > λ1p/(λ1 − λ2), i.e., α < 1. Thus, if p < 0 then 0 < α < 1 and (2.23) is a mixture.
To summarize, when λ1 ≠ λ2, the pdf f(x) is given by (2.23) with α given by (2.24). If p > 0 then (2.23) is either a mixture or a combination of two exponential pdfs, whereas if p < 0 then (2.23) is a mixture.
Again from (2.17)
that is,
(2.25)
With s = 0, (2.25) gives the mean, namely,
(2.26)
The equilibrium pdf thus has Laplace transform, from (2.25) and (2.26), given by
That is,
(2.27)
where
(2.28)