ON THE TAIL BEHAVIOR OF FUNCTIONS OF RANDOM VARIABLES. A.N. Kumar 1, N.S. Upadhye 2. Indian Institute of Technology Madras Chennai, , INDIA
|
|
- Juniper Rudolph Briggs
- 5 years ago
- Views:
Transcription
1 International Journal of Pure and Applied Mathematics Volume 108 No , ISSN: (printed version; ISSN: (on-line version url: doi: /ijpamv108i112 PAijpameu ON THE TAIL BEHAVIOR OF FUNCTIONS OF RANDOM VARIABLES AN Kumar 1, NS Upadhye 2 1,2 Department of Mathematics Indian Institute of Technology Madras Chennai, , INDIA Abstract: It is shown that the tail behavior of the function of nonnegative random variables can be characterized using deterministic functions satisfying certain properties Also, the upper and lower bounds for the tail of product of random variables are given Applications of these results are given to some of the well-known models in economics and risk theory AMS Subject Classification: 60E05, 60E15, 62P20, 91B30, 91B40 Key Words: Natural scale function, Tail behavior, Ruin probability 1 Introduction The tail behavior of functions of random variables (rvs is an important area of research For theoretical development on this topic, see [11, 8, 2] and references therein In applied probability, some of the branches that rely on the analysis of the stochastic model, described by given function(s of rvs, it is important to estimate the behavior for the given function(s of rvs For example, in reliability theory, the tail behavior of failure distribution plays an important role (see [1, 7] In risk modelling, the behavior of the distribution of ruin, for risk model is important (see [9] In this paper, we focus on some aspects of the tail behavior and generalize the existing results for various functions of rvs, such as sum, maximum and product under dependent and independent setup Also, the result for moment and exponential indices follows as a special case of our results, provided they exist Received: January 21, 2016 Published: June 3, 2016 Correspondence author c 2016 Academic Publications, Ltd url: wwwacadpubleu
2 124 AN Kumar, NS Upadhye We next define the necessary terminology required for the discussion Let X be the rv with cumulative distribution function (cdf F X (x Then F X (x = 1 F X (x known as the tail function of X The moment and exponential index, (see [4] and [5], for a rv X are defined as I(X = liminf x E(X = liminf x R X (x ln(x = sup s 0 : E [( X + s ] <, R X (x = sup s 0 : E ( e sx <, x respectively, where x + = max(0,x and R X (x = ln ( FX (x, the hazard function of X A function h : [0, [0, such that h is increasing and h(x as x known as a scale function If h is continuous then we can generalize the definitions of moment and exponential index (see Theorem 21 of [6] as follows (X = liminf x R X (x h(x ( = sup s 0 : E e sh(x <, (1 is called the h-order of X and h is said to be natural scale function if (X = 1 Using this definition, the tail of the rv X can be compared as, for ǫ > 0, F X (x e (1 ǫh(x, (2 and for the rvs X and Y, if liminf x R X (x/r Y (x = c and c > 0 Then the tail comparison (for details, see [6] is given by, for any small ǫ > 0, there exists x N such that for all x > x N, F X (x [ FY (x ] c ǫ (3 Next, we introduce a result of the existence of h satisfying the required properties for discussing the tail behavior of a nonnegative rv Lemma 11 Let X be nonnegative rv Then there exists a monotone concave function h : [0, [0, satisfying h(x = o(x as x and E ( e h(x < Proof It is clear that X is either heavy-tailed or light-tailed rv For heavytailed rv X, Theorem 29 of [11] gives the required result For light-tailed rvs, we can take h(x = x α for any 0 < α < 1 is a monotone concave function satisfying h(x = o(x and Ee h(x < In this paper, we consider nonnegative continuous rvs with right unbounded support, that is, for a rv X, P(X > c > 0 for all c > 0 The structure of the
3 ON THE TAIL BEHAVIOR OF 125 paper is as follows In Section 2, we first prove the theorem to characterize the tail behavior of functions of (dependent or independent rvs, such as sum, maximum and product Next, we derive a method to find the natural scale function for differentiable functions of rvs and use this method to prove the theorem which gives the bounds for the tail of rv XY Finally, in Section 3, we apply the results of Section 2 to Cobb-Douglas production model and discrete time risk model 2 The Moment Index for Sum, Maximum and Product of Random Variables Inthissection, weobtain someoftheresultsaboutthetail behavior offunctions of rvs based on the h-order defined in (1 We exemplify the approach of Lemma 11 to various functions of rvs such as sum, maximum and product in the following results Theorem 21 Let X 1,,X n be nonnegative rvs Then there exists a monotone concave function h and 0 < c 1 c 2 1 such that ( n ( X i = c 1 min (X i max X i = c 2 min (X i 1 i n 1 i n 1 i n Theorem 22 Let X 1,,X n be nonnegative rvs Then there exist functions h and ĥ such that (a min 1 i n (b ( n (c ( n Iĥ(X i ( n X i min 1 i n (X i X i = m min 1 i n (X i, for some m (0,1] X i = r min Iĥ(X i for some r [1, 1 i n Corollaries 21 Let X 1,,X n be independent nonnegative rvs Then there exists a monotone concave function h such that (a ( n X i = min 1 i n (X i
4 126 AN Kumar, NS Upadhye (b (max X i = min (X i 1 i n 1 i n Remarks 21 1 Observethat, if hsatisfies h( n x i n h(x i, the condition of concavity can also be relaxed (see Theorem 4 of [6] 2 If h satisfies h( n x i n h(x i, then we have ( n X i = min 1 i n (X i 3 Observe that, for X = 0 and h(0 = 0, applying (1, we get (0 = sups 0 : E ( e sh(0 < = sups 0 : E(1 < = Also, if for s > 0, either E ( e sh(x 1 ( = ie, (X 1 = 0 or E ( e sh(x 2 = ( ie, (X 2 = 0 Then (X 1 +X 2 = 0 4 Observe also that, if h(x = x or h(x = ln(x (although ln(x is not a scale function, as h : [0, (,, our results for the case of exponential and moment indices follows immediately provided they exist However, our results give flexibility for the choice of h i s 21 Natural Scale Function Recall from (1 that, a scale function h is called natural scale function for a rv X if (X = 1 Next, we describe a method to find the natural scale function for functions of rvs via transformation technique Method Let X 1,,X n be continuous rvs with support S In particular, assume Y 1 = g(x 1,,X n is a differentiable function of n rvs Then, the problem is to find the natural scale function for Y 1 Consider an integral f X1,,X n (x 1,,x n dx 1 dx n, R where R R n Now, take the transformation of the form y 1 = g(x 1,,x n and y i = x i for i = 2,3,,n with support T, together with inverse functions x 1 = w(y 1,,y n and x i = y i for i = 2,3,,n Then, using transformation technique (see [10], pp-124, it is well-known that the joint pdf of rvs Y 1 = g(x 1,,X n, Y 2 = X 2,,Y n = X n is given by f Y1,,Y n (y 1,,y n = J f X1,,X n (w(y 1,,y n,y 2,,y n,
5 ON THE TAIL BEHAVIOR OF 127 where J is the determinant of the Jacobian matrix J Also, the marginal distribution of Y 1 is f Y1 (y 1 = J f X1,,X n (w(y 1,,y n,y 2,,y n dy 2 dy n ( with supp T and the tail function is given by F Y1 (y 1 = y 1 f Y1 (tdt Hence, the natural scale function is h(y 1 = ln ( FY1 (y 1 We can compare the tail of the random variable Y 1 = g(x 1,,X n with the help of natural scale function h That is, FY1 (y 1 = F (g(x 1,,x n e (1 ǫh(y 1 In particular, we have shown that for any differentiable function of g(x 1,,X n, we can find a natural scale function h, such that, for any ǫ > 0, F Y1 (y 1 (the tail function of g is dominated by e (1 ǫh(y 1 Next, we present the upper and lower bounds for the product of two iid rvs Theorem 23 Let X and Y be nonnegative iid rvs Then, for small ǫ > 0, we have the following inequalities, for x > 1, (a If h( = 2R X (, then F XY (x, F X (x e (1 2 ǫh(x (b If h( = R XY (, then F XY (x, F X (x e (1 ǫh(x (c [ FX (x ] 1/(1 ǫ FXY (x [ FX (x ] 1 ǫ Remark 21 In the proof of Theorem 23, the natural scale function h defined in Case 1 and Case 2 are different In Case 1, it is twice the natural scale function of X and in Case 2, it is the natural scale function of XY 3 Applications In this section, we give applications of our results to some well-known models in economics and risk theory 31 Cobb-Douglas Production Model In economics, the Cobb-Douglas production model describes the relationship between the output and input variables This has been widely used since its introduction by Knut Wicksell ( The first significant application of this model is given in [3], where they studied the growth of American economy during the period using
6 128 AN Kumar, NS Upadhye this model, and they were able to present a simplified view of the economy in which the production output is determined by the amount of labor involved and capital invested It is also of importance in economics, to study the long-term behavior of production function in order to formulate certain policies We next describe the mathematical formulation of the Cobb-Douglas model Let T(X,Y = bx α Y β, where T =total production (the monetary value of all goods produced in a year: X =labor involved (the total number of person-hours worked in a year, Y =capital invested (the monetary worth of all machinery, equipment, and buildings, b =total factor productivity, α > 0, β > 0 are the output elasticities of labor and capital, respectively These values are constants determined by available technology We next give the implications of our results to Cobb-Douglas model Now, consider the following conditions on α and β, for a detailed analysis Case (i α + β < 1, there are decreasing return to scale (ie, output decreases proportional to change in inputs Case (ii α + β = 1, there are constant return to scale (ie, output is proportional to change in inputs Case (iii α + β > 1, there are increasing return to scale (ie, output increases proportional to change in inputs Remark 31 Suppose, for any value of b, α and β positive, T(X,Y = bx α Y β, where X and Y are any nonnegative rvs Then using the method given in 21, we can find the dominated function for T We demonstrate this phenomenon through following examples, for various conditions of α and β First, consider for Pareto distribution with parameters a and k, and the condition α β in Cobb-Douglas production model Example 31 Let X and Y are iid Pareto distributed rvs with common pdf f X (x = aka x a+1 where k x < and a,k > 0 Now using technique given in 21 with y 1 = (u /v (u /αv 1/α α/β (1/α 1 β/α g(x,y = x α y β andw(u,v = Hence, it can be easily seen that f(u,v = Therefore, J = (a 2 k 2a /αu (a/α+1 v 1+a (βa/α
7 ON THE TAIL BEHAVIOR OF 129 Since k x,y < implies that k α+β k α v β u ( < Therefore, the marginal distribution of g(x,y is f g(x,y (u = aka (β α 1 /k aα/β u (a/β+1 ( 1 /u (a/α+1 k aβ/α, where k α+β u < The tail function of g(x,y is F ( ( g(x,y (u = ka (β α β /k aα/β u a/β α /u a/α k aβ/α Let ( c = k a/ (β α, then ( / F g(x,y (u = c β k aα/β u a/β ( α /u a/α k aβ/α [ ( and the natural scale function of g(x,y is h(u = ln c β /k aα/β u a/β ( ] α /u a/α k aβ/α From (2, for ǫ > 0 ( F g(x,y (u e (1 ǫh(u = c 1 ǫ β k aα/β u a/β α 1 ǫ u a/α k aβ/α Hence the tail of the production function dominated by the above function for α,β > 0 and α β That is, all three cases (Increasing return to scale, constant return to scale, decreasing return to scale whenever α β tail of the production function dominated by the above function Now, consider the case when α = β = 1 and Theorem 23 for the Pareto distribution Example 32 Suppose X and Y are iid Pareto distributed rv with pdf given by f(x = aka x a+1 where a > 0 and k x < Now using technique given in 21 with y 1 = g(x,y = xy and w(u,v = u/v Therefore, J = 1/v Hence, it is easy to see that f(u,v = ( a 2 k 2a /u a+1 v Since k x < ( implies that k 2 kv u < Also, the marginal pdf of XY is f XY (u = a 2 k 2a ln(u/k 2 /u a+1, wherek 2 u < Thetail function XY is F XY (u = (k 2a( 1+aln(u/k 2 / u a Hence, thenaturalscalefunctionofxy ish XY (u = aln(u ln ( 1+aln ( u/k 2 2aln(k It is clear that XY (X = liminf x R X (x h XY (x = liminf x aln(x aln(k aln(x ln(1+aln( x k 2 2aln(k = 1
8 130 AN Kumar, NS Upadhye Similarly, XY (Y = 1, hence for c = 1, it is satisfied Theorem 21 Compare with production function of Cobb-Douglas model, we have α = β = b = 1 That is, T(X,Y = XY, ie, for x > 1, we have the case in which increasing return to scale, From Theorem 23, the tail function of XY and X are dominated by the function, ( k 2a (1+aln(x/k 2 exp (1 ǫh XY (x = x a 1 ǫ and [ FX (x ] 1/(1 ǫ FXY (x [ FX (x ] 1 ǫ 32 Discrete Time Risk Model Let X i be the net payout of the insurer at year i, and Y i be the discount factor (from year i to i 1 related to the return on the investment, i = 1,2, Then the discounted value of the total risk amount accumulated till the end of year n can be modeled by a discrete time stochastic process W n = n i X i Y j j=1 The basic assumptions for this model (see [9] are as follows A 1 Let A n be the net income within year n Assume A n : n = 1,2, constitute a sequence of iid rvs with support (, A 2 Let r n be the rate of interest on the reserve invested is risky assets Assume r n : n = 1,2, is a sequence of iid rvs with support ( 1, A 3 Also, assume A n : n = 1,2, and r n : n = 1,2, are mutually independent Define B n = 1 + r n, also known as the inflation coefficient from year n 1 to year n and let Y n = Bn 1 be the discount factor from year n to year, n = 1,2, The rvs X = A and Y as the insurance risk and financial risk, respectively Clearly, P(0 < Y < = 1 Let the initial capital of the insurer be x 0 The surplus of the insurer accumulated till the end of year n can be characterized by S n which satisfies the following recurrence equation S 0 = x, S n = B n S +A n,
9 ON THE TAIL BEHAVIOR OF 131 where B n = 1+r n, n = 1,2, The recurrence relation can be written as S 0 = x, S n = x n B j + j=1 n n A i j=i+1 B j, n = 1,2,, (4 where n j=n+1 = 1 Next, the time of ruin for the risk model (4 is defined as τ(x = infn = 1,2, : S n < 0 S 0 = x Hence, the finite time ruin probability, ψ(x,n, and of ultimate ruin probability, ψ(x, can be defined as ψ(x,n = P(τ(x n, respectively, ψ(x = ψ(x, = P(τ(x < Clearly, the probability that the ruin occurs exactly at year n, can be defined as P(τ(x = n = ψ(x,n ψ(x,, n = 1,2, A more significant calculation might be P(τ y (x n or P(τ y (x < for x > 0 and n = 1,2,, where τ y (x is a stopping time, defined by τ y (x = infn = 1,2, : S n y S 0 = x for any regulatory or trigger boundary y 0 This stopping time τ y (x may be interpreted as the first time at which there is a need to raise the capital in order to maintain solvency We can rewrite the discounted value of the surplus S n in as S n 0 = x, Sn = S n Y j = x j=1 n i X i Y j = x W n j=1 Hence, for each n = 0,1,2,, ψ(x,n = P(U n > x, where U n = max0, max 1 k n W k with U 0 = 0 Now, define V 0 = 0, V n = Y n max0,x n +V, n = 1,2, Then Theorem L 21 of [9], it is clear that U n = Vn Hence, the following result shows that the relation ψ(x,n = P(V n > x holds for each n = 1,2, under the assumptions A 1,A 2 and A 3 We next apply ourresults to discussthe tail behavior of U n UsingTheorem 21, Theorem 22 and Corollary 21, there exists a monotone concave function h such that ( = (U n = (max0, max 1 k n W k max 1 k n W k = c n min 1 k n (W k (5 for some constant c n [ 1 n,1] ( i Suppose constant corresponding to k=1 X ( k k j=1 j Y + X i+1 i+1 j=1 Y j is c i, where c i [ 1 2,1] for i = 1,2,,n 1 Now use Theorem 21 in
10 132 AN Kumar, NS Upadhye W 2,W 2,,W n, we get (W j = min 0 k j 1 j 1 ( c i i=k X k+1 k+1 Y l l=1 (6 with assumption that c 0 = 1, combining (5 and (6, we get (U n = c n min 0 k i=k c i ( X k+1 k+1 Y l, (7 where 0 < c i 1, for i = 1,2,, Now, suppose constant corresponding to X i ( i j=1 Y j is k i, i = 1,2,,n Then, we can write X j i j=1 Y j Combining (7 and (8, we get (U n = c n = min min k m+1 0 m l=1 k j (X j,k j ( j Y j (8 ( m+1 c i (X m+1, Y l (9 Now, again takeconstantscorrespondingto( i j=1 Y jy i+1 isd i, i = 1,2,,n 1, where d i (0,1] are some constants ( n Y i = min d i (Y m+1, (10 0 m with assumption d 0 = 1 Combining (9 and (10 (U n = c n min min 0 m min 0 l k m+1 c i (X m+1, min l m k m+1 l=1 m c i d j (Y l+1 (11 The expression given in (11 is a general representation for h-order of U n Further to simplify representation for (11, we consider the following cases j=l
11 ON THE TAIL BEHAVIOR OF 133 Case 1 If we can arrange c i and d i such that d 1 c i1 for i 1 1,2,,n 1,d 2 c i2 for i 2 i 1,, d c i for i i 1 i 2 i n 2 and k n = min 1 p n k p Then Take (U n = c n C = diag min 0 m k 1 i=0 c i,k 2 i=0 k m+1 c i,k 3 c i (X m+1,k n c i=2 c i,,k n c i=2 d i (Y m+1 D = diag k n c d i,k n c d i,k n c d i,,k n c d X = (X 1,X 2,,X n and Y = (Y 1,Y 2,,Y n Then (U n = c n min (XC, (YD Case 2 If we can arrange c i and d i such that c 1 d i1 for i 1 1,2,,n 1, c 2 d i2 for i 2 i 1,, c d i for i i 1 i 2 i n 2 Then (U n = c n min 0 m k m+1 c i (X m+1,k 2 d 1 c i (Y 1,k m+1 d m c i (Y m+1 Take Then C = diag k 1 c i,k 2 c i,k 3 i=2 c i,,k n c D = diag k 2 d 1 c i,k 2 d 1 c i,k 3 d 2 c i,,k n c d i=2 (U n = c n min (XC, (YD
12 134 AN Kumar, NS Upadhye Remark 32 If X 1,X 2,,X n are iid rvs and Y 1,Y 2,,Y n are also iid rvs Then for Case 1, we have (U n = c n min k n c d i (Y 1,mink 1,k 2 c i (X 1, and for Case 2, (U n = c n min k 2 d 1 c i (Y 1,mink 1,k 2 c i (X 1 which are very easy to calculate Remark 33 Observe that, from Theorem 21, Theorem 22 and Corollary 21, if the natural scale function of X i and Y i are h Xi and h Yi respectively, then the scale function for U n is given by h(x = n ( h Xi (x+(n i+1h Yi (x Next we consider the tail behavior of V n, defined as V n = Y n max0,x n +V Now let the constants between (Y i (max0,x i +V i 1 and (X j +(V j 1 are c i and d i respectively, where c i (0,1] and d j [ 1 2,1] for i = 1,2,,n and j = 2,3,,n Hence, (V n = minc n (Y n,c n (0,X n +V = minc n (Y n,c n (X n +V = minc n (Y n,c n d n (X n,c n d n (V n = min c i d i (X m, 1 m n n c i d i+1 (Y m (12 We assume in above expression that d n+1 = 1 = d 1 Now take n C = diag c i d i+1,,c n d n
13 ON THE TAIL BEHAVIOR OF 135 and Hence, we get n D = diag c i d i+1,,c n (V n = min (XC, (YD Remark 34 If X 1,X 2,,X n are iid rvs and Y 1,Y 2,,Y n are also iid rvs Then (V n = n c id i+1 min (X 1, (Y 1,whichiseasytocalculate We know that V n = Y n max0,x n +V If the scale function of X i and Y i are h Xi and h Yi respectively Then, using Theorem 21, Theorem 22 and Corollary 21, the scale function h for V n is given by h(x = n (h Xi +h Yi Remark 35 As mentioned earlier, U n and V n have same distribution and it can be seen from (11 and (13, the representation of V n is preferable over the representation of U n due to the ease of computation and simplicity in the construction of h 4 Proofs Proof of Theorem 21 Since X 1,,X n are nonnegative rvs Using Lemma 11, thereexistmonotoneconcave functionsh 1,,h n suchthate ( e h i(x < and h i (x = o(x as x, for i = 1,,n Define h(x = n h i (x n h i (0, therefore, h is a monotone concave function and h(0 = 0 Hence, by Remark 2 of [6], h is continuous and increasing function with h(x 1 +x 2 h(x 1 +h(x 2 for all x 1,x 2 > 0 We know that max 1 i n x i x i for i = 1,,n, this implies for s > 0, we have ( ( E e sh(max 1 i n X i E e sh(x i Therefore, (max 1 i n X i (X i Hence, (max 1 i n X i min 1 i n (X i (13
14 136 AN Kumar, NS Upadhye Similarly, it is easy to see that ( n X i (max X i 1 i n (14 Hence combine (14 and (15, we get required result Proof of Theorem 22 Using Lemma 11, there exist monotone concave functions h 1,,h n such that E ( e h i(x < and h i (x = o(x as x, for i = 1,,n Let h(x = n h i(x n h i(0, therefore, h is monotone concave with h(0 = 0 For i = 1,,n, define ĥ(x i = x h(x i, where x = max 1 i n x i +1 It is clear that x i x n x i, This implies ( n ( h(x i h x i /x 1 n x h x i That is, Therefore, ( n h x i x h(x i = ĥ(x i E (e sh( n X i ( E e sĥ(x i Hence, Now, consider E (e sh( n X i ( n X i min Iĥ(X i 1 i n E (e sh( n X i 1(X2 1,,X n 1 E (e n sh(x 1 P(X i 1, we get ( n X i (X 1, similarly, for i = 2,,n, ( n X i (X i Hence, ( n X i min 1 i n (X i Hence, min 1 i n Iĥ(X i ( n X i min 1 i n (X i i=2
15 ON THE TAIL BEHAVIOR OF 137 This proves (a It is easy to see that Iĥ(X i (X i, for i = 1,,n Choose c 1 such that ciĥ(x i (X i, therefore, 1 c min I h(x i min Iĥ(X i ( n X i 1 i n 1 i n min 1 i n (X i c min 1 i n Iĥ(X i Hence, there exist m (0,1] and r [1, such that ( n ( n X i = m min I h(x i and X i = r min Iĥ(X i 1 i n 1 i n This proves (b and (c Proof of Corollary 21 It follows from the proof of Theorem 21, ( n X i min 1 i n (X i To prove the equality, it is known that h( n x i n h(x i and X i are independent rvs Then E (e sh( n X i n E( e sh(x i Therefore, ( n X i min 1 i n (X i Hence, ( n This proves (a Next, from (14, we know that (max X i 1 i n Now, it is clear that this implies X i = min 1 i n (X i max x i 1 i n min 1 i n (X i n x i, ( E e sh(max 1 i nx i E (e sh( n X i n ( E e sh(x i
16 138 AN Kumar, NS Upadhye Therefore, Hence, This proves (b (max X i min (X i 1 i n 1 i n (max X i = min (X i 1 i n 1 i n Proof of Theorem 23 Recall from Theorem 22 and Remarks 21, we have (XY = min( (X, (Y For iid rvs (X = (Y Hence, (XY = (X Then we can find the tail behavior of the rvs in the following ways Case 1 Suppose h 1 is a natural scale function of X, therefore h = 2h 1 and (X = (X = 1/2 Then (XY = (X = 1/2, for small ǫ > 0, using the definition of lim inf, F XY (x, F X (x e (1 2 ǫh(x This proves (a Since, h 1 isthenaturalscalefunctionx, therefore, h(x = 2h 1 (x = 2R X (x and (XY = 1/2, hence, that is, From (3, lim inf x lim inf x R XY (x 2R X (x = 1/2, R XY (x R X (x = 1 F XY (x [ FX (x ] 1 ǫ (15 Case 2 Using the method described in 21, we can find the natural scale function h for XY then (XY = (X = 1 Using the definition of liminf, for ǫ > 0, F XY (x, F X (x e (1 ǫh(x This proves (b Next, note that h is the natural scale function XY, therefore, h(x = R XY (x and (XY = (X = 1, that is, (X = 1, hence, lim inf x R X (x R XY (x = 1
17 ON THE TAIL BEHAVIOR OF 139 Therefore, from (3, F X (x [ FXY (x ] 1 ǫ (16 Combining (16 and (17, it is clear that [ FX (x ] 1/(1 ǫ FXY (x [ FX (x ] 1 ǫ This proves (c References [1] AA Balkema, L DeHaan, Residual Lifetime at Great Age, Ann Prob, 2 (1974, [2] C Yu, Y Wang, D Cheng, Tail behavior of the sums of dependent and heavy-tailed random variables, To appear in Journal of the Korean Statistical Society, (2014 [3] C W Cobb, P H Douglas, A Theory of Production, American Economic Review, 18 (1928, [4] D J Daley, The moment index of minima, J Appl Prob, 38 (2001, [5] D J Daley, C M Goldie, The moment index of minima (II, Statistics & Probability Letters, 76 (2006, [6] J Lehtomaa, A comparison method for heavy-tailed random variables, Preprint arxiv: , (2013 [7] M C Bhattachaijee, Tail Behavior of Age-Smooth Failure Distributions and Applications, Reliability and Quality Control, ed A PBasu, Amsterdam, North-Holland (1986 [8] P C H Phillips, A Theorem on the Tail Behaviour of Probability Distributions with an Application to the Stable Family, The Canadian Journal of Economics, 18 (1985, [9] Q Tang, G Tsitsiashvili, Precise estimates for the ruin probability in finite horizon in a discrete-time model with heavy-tailed insurance and financial risk, toch Proc Appl, 108 (2003, [10] R V Hogg, J W McKean, A T Craig, Introduction to mathematical statistics (sixth edition, Prentice Hall, Upper Saddle River, New Jersey (2005 [11] S Foss, D Korshunov, S Zachary, An introduction to heavy-tailed and subexponential distributions, Springer Verlag, New York (2011
18 140
Asymptotics of random sums of heavy-tailed negatively dependent random variables with applications
Asymptotics of random sums of heavy-tailed negatively dependent random variables with applications Remigijus Leipus (with Yang Yang, Yuebao Wang, Jonas Šiaulys) CIRM, Luminy, April 26-30, 2010 1. Preliminaries
More informationReinsurance and ruin problem: asymptotics in the case of heavy-tailed claims
Reinsurance and ruin problem: asymptotics in the case of heavy-tailed claims Serguei Foss Heriot-Watt University, Edinburgh Karlovasi, Samos 3 June, 2010 (Joint work with Tomasz Rolski and Stan Zachary
More informationScandinavian Actuarial Journal. Asymptotics for ruin probabilities in a discrete-time risk model with dependent financial and insurance risks
Asymptotics for ruin probabilities in a discrete-time risk model with dependent financial and insurance risks For eer Review Only Journal: Manuscript ID: SACT-- Manuscript Type: Original Article Date Submitted
More informationarxiv: v1 [math.pr] 9 May 2014
On asymptotic scales of independently stopped random sums Jaakko Lehtomaa arxiv:1405.2239v1 [math.pr] 9 May 2014 May 12, 2014 Abstract We study randomly stopped sums via their asymptotic scales. First,
More informationAsymptotic behavior for sums of non-identically distributed random variables
Appl. Math. J. Chinese Univ. 2019, 34(1: 45-54 Asymptotic behavior for sums of non-identically distributed random variables YU Chang-jun 1 CHENG Dong-ya 2,3 Abstract. For any given positive integer m,
More informationFinite-time Ruin Probability of Renewal Model with Risky Investment and Subexponential Claims
Proceedings of the World Congress on Engineering 29 Vol II WCE 29, July 1-3, 29, London, U.K. Finite-time Ruin Probability of Renewal Model with Risky Investment and Subexponential Claims Tao Jiang Abstract
More informationComonotonicity and Maximal Stop-Loss Premiums
Comonotonicity and Maximal Stop-Loss Premiums Jan Dhaene Shaun Wang Virginia Young Marc J. Goovaerts November 8, 1999 Abstract In this paper, we investigate the relationship between comonotonicity and
More informationThe Subexponential Product Convolution of Two Weibull-type Distributions
The Subexponential Product Convolution of Two Weibull-type Distributions Yan Liu School of Mathematics and Statistics Wuhan University Wuhan, Hubei 4372, P.R. China E-mail: yanliu@whu.edu.cn Qihe Tang
More informationPrecise Estimates for the Ruin Probability in Finite Horizon in a Discrete-time Model with Heavy-tailed Insurance and Financial Risks
Precise Estimates for the Ruin Probability in Finite Horizon in a Discrete-time Model with Heavy-tailed Insurance and Financial Risks Qihe Tang Department of Quantitative Economics University of Amsterdam
More informationResearch Reports on Mathematical and Computing Sciences
ISSN 1342-2804 Research Reports on Mathematical and Computing Sciences Long-tailed degree distribution of a random geometric graph constructed by the Boolean model with spherical grains Naoto Miyoshi,
More informationWEIGHTED SUMS OF SUBEXPONENTIAL RANDOM VARIABLES AND THEIR MAXIMA
Adv. Appl. Prob. 37, 510 522 2005 Printed in Northern Ireland Applied Probability Trust 2005 WEIGHTED SUMS OF SUBEXPONENTIAL RANDOM VARIABLES AND THEIR MAXIMA YIQING CHEN, Guangdong University of Technology
More informationRandomly Weighted Sums of Conditionnally Dependent Random Variables
Gen. Math. Notes, Vol. 25, No. 1, November 2014, pp.43-49 ISSN 2219-7184; Copyright c ICSRS Publication, 2014 www.i-csrs.org Available free online at http://www.geman.in Randomly Weighted Sums of Conditionnally
More informationMath 3215 Intro. Probability & Statistics Summer 14. Homework 5: Due 7/3/14
Math 325 Intro. Probability & Statistics Summer Homework 5: Due 7/3/. Let X and Y be continuous random variables with joint/marginal p.d.f. s f(x, y) 2, x y, f (x) 2( x), x, f 2 (y) 2y, y. Find the conditional
More informationCharacterization through Hazard Rate of heavy tailed distributions and some Convolution Closure Properties
Characterization through Hazard Rate of heavy tailed distributions and some Convolution Closure Properties Department of Statistics and Actuarial - Financial Mathematics, University of the Aegean October
More informationRuin probabilities in multivariate risk models with periodic common shock
Ruin probabilities in multivariate risk models with periodic common shock January 31, 2014 3 rd Workshop on Insurance Mathematics Universite Laval, Quebec, January 31, 2014 Ruin probabilities in multivariate
More informationContinuous Random Variables
1 / 24 Continuous Random Variables Saravanan Vijayakumaran sarva@ee.iitb.ac.in Department of Electrical Engineering Indian Institute of Technology Bombay February 27, 2013 2 / 24 Continuous Random Variables
More informationUniversity Of Calgary Department of Mathematics and Statistics
University Of Calgary Department of Mathematics and Statistics Hawkes Seminar May 23, 2018 1 / 46 Some Problems in Insurance and Reinsurance Mohamed Badaoui Department of Electrical Engineering National
More informationRare Events in Random Walks and Queueing Networks in the Presence of Heavy-Tailed Distributions
Rare Events in Random Walks and Queueing Networks in the Presence of Heavy-Tailed Distributions Sergey Foss Heriot-Watt University, Edinburgh and Institute of Mathematics, Novosibirsk The University of
More information4. Distributions of Functions of Random Variables
4. Distributions of Functions of Random Variables Setup: Consider as given the joint distribution of X 1,..., X n (i.e. consider as given f X1,...,X n and F X1,...,X n ) Consider k functions g 1 : R n
More informationRare event simulation for the ruin problem with investments via importance sampling and duality
Rare event simulation for the ruin problem with investments via importance sampling and duality Jerey Collamore University of Copenhagen Joint work with Anand Vidyashankar (GMU) and Guoqing Diao (GMU).
More informationCHARACTERIZATIONS OF THE PARETO DISTRIBUTION BY THE INDEPENDENCE OF RECORD VALUES. Se-Kyung Chang* 1. Introduction
JOURNAL OF THE CHUNGCHEONG MATHEMATICAL SOCIETY Volume 20, No., March 2007 CHARACTERIZATIONS OF THE PARETO DISTRIBUTION BY THE INDEPENDENCE OF RECORD VALUES Se-Kyung Chang* Abstract. In this paper, we
More informationAsymptotic Tail Probabilities of Sums of Dependent Subexponential Random Variables
Asymptotic Tail Probabilities of Sums of Dependent Subexponential Random Variables Jaap Geluk 1 and Qihe Tang 2 1 Department of Mathematics The Petroleum Institute P.O. Box 2533, Abu Dhabi, United Arab
More informationECE 4400:693 - Information Theory
ECE 4400:693 - Information Theory Dr. Nghi Tran Lecture 8: Differential Entropy Dr. Nghi Tran (ECE-University of Akron) ECE 4400:693 Lecture 1 / 43 Outline 1 Review: Entropy of discrete RVs 2 Differential
More information2. The CDF Technique. 1. Introduction. f X ( ).
Week 5: Distributions of Function of Random Variables. Introduction Suppose X,X 2,..., X n are n random variables. In this chapter, we develop techniques that may be used to find the distribution of functions
More informationMathematics for Economics ECON MA/MSSc in Economics-2017/2018. Dr. W. M. Semasinghe Senior Lecturer Department of Economics
Mathematics for Economics ECON 53035 MA/MSSc in Economics-2017/2018 Dr. W. M. Semasinghe Senior Lecturer Department of Economics MATHEMATICS AND STATISTICS LERNING OUTCOMES: By the end of this course unit
More informationOn Upper Bounds for the Tail Distribution of Geometric Sums of Subexponential Random Variables
On Upper Bounds for the Tail Distribution of Geometric Sums of Subexponential Random Variables Andrew Richards arxiv:0805.4548v2 [math.pr] 18 Mar 2009 Department of Actuarial Mathematics and Statistics
More informationExercises with solutions (Set D)
Exercises with solutions Set D. A fair die is rolled at the same time as a fair coin is tossed. Let A be the number on the upper surface of the die and let B describe the outcome of the coin toss, where
More informationMonotonicity and Aging Properties of Random Sums
Monotonicity and Aging Properties of Random Sums Jun Cai and Gordon E. Willmot Department of Statistics and Actuarial Science University of Waterloo Waterloo, Ontario Canada N2L 3G1 E-mail: jcai@uwaterloo.ca,
More informationQingwu Gao and Yang Yang
Bull. Korean Math. Soc. 50 2013, No. 2, pp. 611 626 http://dx.doi.org/10.4134/bkms.2013.50.2.611 UNIFORM ASYMPTOTICS FOR THE FINITE-TIME RUIN PROBABILITY IN A GENERAL RISK MODEL WITH PAIRWISE QUASI-ASYMPTOTICALLY
More informationIntroduction to Statistical Inference Self-study
Introduction to Statistical Inference Self-study Contents Definition, sample space The fundamental object in probability is a nonempty sample space Ω. An event is a subset A Ω. Definition, σ-algebra A
More informationMarshall-Olkin Bivariate Exponential Distribution: Generalisations and Applications
CHAPTER 6 Marshall-Olkin Bivariate Exponential Distribution: Generalisations and Applications 6.1 Introduction Exponential distributions have been introduced as a simple model for statistical analysis
More informationA New Class of Positively Quadrant Dependent Bivariate Distributions with Pareto
International Mathematical Forum, 2, 27, no. 26, 1259-1273 A New Class of Positively Quadrant Dependent Bivariate Distributions with Pareto A. S. Al-Ruzaiza and Awad El-Gohary 1 Department of Statistics
More informationThe Ruin Probability of a Discrete Time Risk Model under Constant Interest Rate with Heavy Tails
Scand. Actuarial J. 2004; 3: 229/240 æoriginal ARTICLE The Ruin Probability of a Discrete Time Risk Model under Constant Interest Rate with Heavy Tails QIHE TANG Qihe Tang. The ruin probability of a discrete
More informationChapter 3 sections. SKIP: 3.10 Markov Chains. SKIP: pages Chapter 3 - continued
Chapter 3 sections Chapter 3 - continued 3.1 Random Variables and Discrete Distributions 3.2 Continuous Distributions 3.3 The Cumulative Distribution Function 3.4 Bivariate Distributions 3.5 Marginal Distributions
More informationUniversity of Warwick, EC9A0 Maths for Economists Lecture Notes 10: Dynamic Programming
University of Warwick, EC9A0 Maths for Economists 1 of 63 University of Warwick, EC9A0 Maths for Economists Lecture Notes 10: Dynamic Programming Peter J. Hammond Autumn 2013, revised 2014 University of
More informationStochastic Comparisons of Weighted Sums of Arrangement Increasing Random Variables
Portland State University PDXScholar Mathematics and Statistics Faculty Publications and Presentations Fariborz Maseeh Department of Mathematics and Statistics 4-7-2015 Stochastic Comparisons of Weighted
More information2 Functions of random variables
2 Functions of random variables A basic statistical model for sample data is a collection of random variables X 1,..., X n. The data are summarised in terms of certain sample statistics, calculated as
More information1 Probability and Random Variables
1 Probability and Random Variables The models that you have seen thus far are deterministic models. For any time t, there is a unique solution X(t). On the other hand, stochastic models will result in
More informationLecture 2. We now introduce some fundamental tools in martingale theory, which are useful in controlling the fluctuation of martingales.
Lecture 2 1 Martingales We now introduce some fundamental tools in martingale theory, which are useful in controlling the fluctuation of martingales. 1.1 Doob s inequality We have the following maximal
More informationOn Sums of Conditionally Independent Subexponential Random Variables
On Sums of Conditionally Independent Subexponential Random Variables arxiv:86.49v1 [math.pr] 3 Jun 28 Serguei Foss 1 and Andrew Richards 1 The asymptotic tail-behaviour of sums of independent subexponential
More informationStability of the Defect Renewal Volterra Integral Equations
19th International Congress on Modelling and Simulation, Perth, Australia, 12 16 December 211 http://mssanz.org.au/modsim211 Stability of the Defect Renewal Volterra Integral Equations R. S. Anderssen,
More informationResearch Article Extended Precise Large Deviations of Random Sums in the Presence of END Structure and Consistent Variation
Applied Mathematics Volume 2012, Article ID 436531, 12 pages doi:10.1155/2012/436531 Research Article Extended Precise Large Deviations of Random Sums in the Presence of END Structure and Consistent Variation
More informationDistributions of Functions of Random Variables. 5.1 Functions of One Random Variable
Distributions of Functions of Random Variables 5.1 Functions of One Random Variable 5.2 Transformations of Two Random Variables 5.3 Several Random Variables 5.4 The Moment-Generating Function Technique
More informationLecture 21: Convergence of transformations and generating a random variable
Lecture 21: Convergence of transformations and generating a random variable If Z n converges to Z in some sense, we often need to check whether h(z n ) converges to h(z ) in the same sense. Continuous
More informationStat 5101 Notes: Algorithms
Stat 5101 Notes: Algorithms Charles J. Geyer January 22, 2016 Contents 1 Calculating an Expectation or a Probability 3 1.1 From a PMF........................... 3 1.2 From a PDF...........................
More informationRuin Probabilities of a Discrete-time Multi-risk Model
Ruin Probabilities of a Discrete-time Multi-risk Model Andrius Grigutis, Agneška Korvel, Jonas Šiaulys Faculty of Mathematics and Informatics, Vilnius University, Naugarduko 4, Vilnius LT-035, Lithuania
More informationReliability of Coherent Systems with Dependent Component Lifetimes
Reliability of Coherent Systems with Dependent Component Lifetimes M. Burkschat Abstract In reliability theory, coherent systems represent a classical framework for describing the structure of technical
More informationGeneralized quantiles as risk measures
Generalized quantiles as risk measures Bellini, Klar, Muller, Rosazza Gianin December 1, 2014 Vorisek Jan Introduction Quantiles q α of a random variable X can be defined as the minimizers of a piecewise
More informationEEL 5544 Noise in Linear Systems Lecture 30. X (s) = E [ e sx] f X (x)e sx dx. Moments can be found from the Laplace transform as
L30-1 EEL 5544 Noise in Linear Systems Lecture 30 OTHER TRANSFORMS For a continuous, nonnegative RV X, the Laplace transform of X is X (s) = E [ e sx] = 0 f X (x)e sx dx. For a nonnegative RV, the Laplace
More informationReview: mostly probability and some statistics
Review: mostly probability and some statistics C2 1 Content robability (should know already) Axioms and properties Conditional probability and independence Law of Total probability and Bayes theorem Random
More informationRandomly weighted sums under a wide type of dependence structure with application to conditional tail expectation
Randomly weighted sums under a wide type of dependence structure with application to conditional tail expectation Shijie Wang a, Yiyu Hu a, Lianqiang Yang a, Wensheng Wang b a School of Mathematical Sciences,
More informationSoftware Reliability & Testing
Repairable systems Repairable system A reparable system is obtained by glueing individual non-repairable systems each around a single failure To describe this gluing process we need to review the concept
More informationBMIR Lecture Series on Probability and Statistics Fall 2015 Discrete RVs
Lecture #7 BMIR Lecture Series on Probability and Statistics Fall 2015 Department of Biomedical Engineering and Environmental Sciences National Tsing Hua University 7.1 Function of Single Variable Theorem
More informationRandom Variables. Random variables. A numerically valued map X of an outcome ω from a sample space Ω to the real line R
In probabilistic models, a random variable is a variable whose possible values are numerical outcomes of a random phenomenon. As a function or a map, it maps from an element (or an outcome) of a sample
More informationIntroduction to Probability and Statistics (Continued)
Introduction to Probability and Statistics (Continued) Prof. icholas Zabaras Center for Informatics and Computational Science https://cics.nd.edu/ University of otre Dame otre Dame, Indiana, USA Email:
More informationAlmost sure convergence to zero in stochastic growth models
Forthcoming in Economic Theory Almost sure convergence to zero in stochastic growth models Takashi Kamihigashi RIEB, Kobe University, Rokkodai, Nada, Kobe 657-8501, Japan (email: tkamihig@rieb.kobe-u.ac.jp)
More informationJoint Distributions. (a) Scalar multiplication: k = c d. (b) Product of two matrices: c d. (c) The transpose of a matrix:
Joint Distributions Joint Distributions A bivariate normal distribution generalizes the concept of normal distribution to bivariate random variables It requires a matrix formulation of quadratic forms,
More informationStatistics for scientists and engineers
Statistics for scientists and engineers February 0, 006 Contents Introduction. Motivation - why study statistics?................................... Examples..................................................3
More informationComparing downside risk measures for heavy tailed distributions
Comparing downside risk measures for heavy tailed distributions Jon Danielsson Bjorn N. Jorgensen Mandira Sarma Casper G. de Vries March 6, 2005 Abstract In this paper we study some prominent downside
More informationconditional cdf, conditional pdf, total probability theorem?
6 Multiple Random Variables 6.0 INTRODUCTION scalar vs. random variable cdf, pdf transformation of a random variable conditional cdf, conditional pdf, total probability theorem expectation of a random
More informationMAS223 Statistical Inference and Modelling Exercises
MAS223 Statistical Inference and Modelling Exercises The exercises are grouped into sections, corresponding to chapters of the lecture notes Within each section exercises are divided into warm-up questions,
More informationStructural Reliability
Structural Reliability Thuong Van DANG May 28, 2018 1 / 41 2 / 41 Introduction to Structural Reliability Concept of Limit State and Reliability Review of Probability Theory First Order Second Moment Method
More informationNecessary and sucient condition for the boundedness of the Gerber-Shiu function in dependent Sparre Andersen model
Miskolc Mathematical Notes HU e-issn 1787-2413 Vol. 15 (214), No 1, pp. 159-17 OI: 1.18514/MMN.214.757 Necessary and sucient condition for the boundedness of the Gerber-Shiu function in dependent Sparre
More informationFormulas for probability theory and linear models SF2941
Formulas for probability theory and linear models SF2941 These pages + Appendix 2 of Gut) are permitted as assistance at the exam. 11 maj 2008 Selected formulae of probability Bivariate probability Transforms
More informationWEIBULL RENEWAL PROCESSES
Ann. Inst. Statist. Math. Vol. 46, No. 4, 64-648 (994) WEIBULL RENEWAL PROCESSES NIKOS YANNAROS Department of Statistics, University of Stockholm, S-06 9 Stockholm, Sweden (Received April 9, 993; revised
More informationPart IA Probability. Definitions. Based on lectures by R. Weber Notes taken by Dexter Chua. Lent 2015
Part IA Probability Definitions Based on lectures by R. Weber Notes taken by Dexter Chua Lent 2015 These notes are not endorsed by the lecturers, and I have modified them (often significantly) after lectures.
More informationSTAT 512 sp 2018 Summary Sheet
STAT 5 sp 08 Summary Sheet Karl B. Gregory Spring 08. Transformations of a random variable Let X be a rv with support X and let g be a function mapping X to Y with inverse mapping g (A = {x X : g(x A}
More informationA Note on Tail Behaviour of Distributions. the max domain of attraction of the Frechét / Weibull law under power normalization
ProbStat Forum, Volume 03, January 2010, Pages 01-10 ISSN 0974-3235 A Note on Tail Behaviour of Distributions in the Max Domain of Attraction of the Frechét/ Weibull Law under Power Normalization S.Ravi
More informationOn Differentiability of Average Cost in Parameterized Markov Chains
On Differentiability of Average Cost in Parameterized Markov Chains Vijay Konda John N. Tsitsiklis August 30, 2002 1 Overview The purpose of this appendix is to prove Theorem 4.6 in 5 and establish various
More informationDeccan Education Society s FERGUSSON COLLEGE, PUNE (AUTONOMOUS) SYLLABUS UNDER AUTOMONY. SECOND YEAR B.Sc. SEMESTER - III
Deccan Education Society s FERGUSSON COLLEGE, PUNE (AUTONOMOUS) SYLLABUS UNDER AUTOMONY SECOND YEAR B.Sc. SEMESTER - III SYLLABUS FOR S. Y. B. Sc. STATISTICS Academic Year 07-8 S.Y. B.Sc. (Statistics)
More informationMultiple Random Variables
Multiple Random Variables Joint Probability Density Let X and Y be two random variables. Their joint distribution function is F ( XY x, y) P X x Y y. F XY ( ) 1, < x
More informationChapter 3 sections. SKIP: 3.10 Markov Chains. SKIP: pages Chapter 3 - continued
Chapter 3 sections 3.1 Random Variables and Discrete Distributions 3.2 Continuous Distributions 3.3 The Cumulative Distribution Function 3.4 Bivariate Distributions 3.5 Marginal Distributions 3.6 Conditional
More informationOn Finite-Time Ruin Probabilities in a Risk Model Under Quota Share Reinsurance
Applied Mathematical Sciences, Vol. 11, 217, no. 53, 269-2629 HIKARI Ltd, www.m-hikari.com https://doi.org/1.12988/ams.217.7824 On Finite-Time Ruin Probabilities in a Risk Model Under Quota Share Reinsurance
More informationECE 650 Lecture 4. Intro to Estimation Theory Random Vectors. ECE 650 D. Van Alphen 1
EE 650 Lecture 4 Intro to Estimation Theory Random Vectors EE 650 D. Van Alphen 1 Lecture Overview: Random Variables & Estimation Theory Functions of RV s (5.9) Introduction to Estimation Theory MMSE Estimation
More informationBasic concepts of probability theory
Basic concepts of probability theory Random variable discrete/continuous random variable Transform Z transform, Laplace transform Distribution Geometric, mixed-geometric, Binomial, Poisson, exponential,
More information5. Random Vectors. probabilities. characteristic function. cross correlation, cross covariance. Gaussian random vectors. functions of random vectors
EE401 (Semester 1) 5. Random Vectors Jitkomut Songsiri probabilities characteristic function cross correlation, cross covariance Gaussian random vectors functions of random vectors 5-1 Random vectors we
More informationAPPM/MATH 4/5520 Solutions to Problem Set Two. = 2 y = y 2. e 1 2 x2 1 = 1. (g 1
APPM/MATH 4/552 Solutions to Problem Set Two. Let Y X /X 2 and let Y 2 X 2. (We can select Y 2 to be anything but when dealing with a fraction for Y, it is usually convenient to set Y 2 to be the denominator.)
More informationThis exam contains 13 pages (including this cover page) and 10 questions. A Formulae sheet is provided with the exam.
Probability and Statistics FS 2017 Session Exam 22.08.2017 Time Limit: 180 Minutes Name: Student ID: This exam contains 13 pages (including this cover page) and 10 questions. A Formulae sheet is provided
More informationStatic Problem Set 2 Solutions
Static Problem Set Solutions Jonathan Kreamer July, 0 Question (i) Let g, h be two concave functions. Is f = g + h a concave function? Prove it. Yes. Proof: Consider any two points x, x and α [0, ]. Let
More informationOn lower limits and equivalences for distribution tails of randomly stopped sums 1
On lower limits and equivalences for distribution tails of randomly stopped sums 1 D. Denisov, 2 S. Foss, 3 and D. Korshunov 4 Eurandom, Heriot-Watt University and Sobolev Institute of Mathematics Abstract
More informationAsymptotic Ruin Probabilities for a Bivariate Lévy-driven Risk Model with Heavy-tailed Claims and Risky Investments
Asymptotic Ruin robabilities for a Bivariate Lévy-driven Risk Model with Heavy-tailed Claims and Risky Investments Xuemiao Hao and Qihe Tang Asper School of Business, University of Manitoba 181 Freedman
More informationJoint Probability Distributions and Random Samples (Devore Chapter Five)
Joint Probability Distributions and Random Samples (Devore Chapter Five) 1016-345-01: Probability and Statistics for Engineers Spring 2013 Contents 1 Joint Probability Distributions 2 1.1 Two Discrete
More informationE X A M. Probability Theory and Stochastic Processes Date: December 13, 2016 Duration: 4 hours. Number of pages incl.
E X A M Course code: Course name: Number of pages incl. front page: 6 MA430-G Probability Theory and Stochastic Processes Date: December 13, 2016 Duration: 4 hours Resources allowed: Notes: Pocket calculator,
More informationWald for non-stopping times: The rewards of impatient prophets
Electron. Commun. Probab. 19 (2014), no. 78, 1 9. DOI: 10.1214/ECP.v19-3609 ISSN: 1083-589X ELECTRONIC COMMUNICATIONS in PROBABILITY Wald for non-stopping times: The rewards of impatient prophets Alexander
More informationON THE HÖLDER CONTINUITY OF MATRIX FUNCTIONS FOR NORMAL MATRICES
Volume 10 (2009), Issue 4, Article 91, 5 pp. ON THE HÖLDER CONTINUITY O MATRIX UNCTIONS OR NORMAL MATRICES THOMAS P. WIHLER MATHEMATICS INSTITUTE UNIVERSITY O BERN SIDLERSTRASSE 5, CH-3012 BERN SWITZERLAND.
More informationAPPM/MATH 4/5520 Solutions to Exam I Review Problems. f X 1,X 2. 2e x 1 x 2. = x 2
APPM/MATH 4/5520 Solutions to Exam I Review Problems. (a) f X (x ) f X,X 2 (x,x 2 )dx 2 x 2e x x 2 dx 2 2e 2x x was below x 2, but when marginalizing out x 2, we ran it over all values from 0 to and so
More informationQuantile-quantile plots and the method of peaksover-threshold
Problems in SF2980 2009-11-09 12 6 4 2 0 2 4 6 0.15 0.10 0.05 0.00 0.05 0.10 0.15 Figure 2: qqplot of log-returns (x-axis) against quantiles of a standard t-distribution with 4 degrees of freedom (y-axis).
More informationMeasure-theoretic probability
Measure-theoretic probability Koltay L. VEGTMAM144B November 28, 2012 (VEGTMAM144B) Measure-theoretic probability November 28, 2012 1 / 27 The probability space De nition The (Ω, A, P) measure space is
More informationSize-biased discrete two parameter Poisson-Lindley Distribution for modeling and waiting survival times data
IOSR Journal of Mathematics (IOSR-JM) e-issn: 2278-5728, p-issn:2319-765x. Volume 10, Issue 1 Ver. III. (Feb. 2014), PP 39-45 Size-biased discrete two parameter Poisson-Lindley Distribution for modeling
More informationRFID & Item-Level Information Visibility
Department of Information System & Operations Management University of Florida Gainesville, Florida 32601 wzhou@ufl.edu December 13, 2008 1. Manufacturing an Engine Engine Builder Replenish Policy {A1,A2}
More informationBasics of Stochastic Modeling: Part II
Basics of Stochastic Modeling: Part II Continuous Random Variables 1 Sandip Chakraborty Department of Computer Science and Engineering, INDIAN INSTITUTE OF TECHNOLOGY KHARAGPUR August 10, 2016 1 Reference
More informationASYMPTOTIC BEHAVIOR OF THE FINITE-TIME RUIN PROBABILITY WITH PAIRWISE QUASI-ASYMPTOTICALLY INDEPENDENT CLAIMS AND CONSTANT INTEREST FORCE
ROCKY MOUNTAIN JOURNAL OF MATHEMATICS Volume 44, Number 5, 214 ASYMPTOTIC BEHAVIOR OF THE FINITE-TIME RUIN PROBABILITY WITH PAIRWISE QUASI-ASYMPTOTICALLY INDEPENDENT CLAIMS AND CONSTANT INTEREST FORCE
More informationA COMPOUND POISSON APPROXIMATION INEQUALITY
J. Appl. Prob. 43, 282 288 (2006) Printed in Israel Applied Probability Trust 2006 A COMPOUND POISSON APPROXIMATION INEQUALITY EROL A. PEKÖZ, Boston University Abstract We give conditions under which the
More information3 Continuous Random Variables
Jinguo Lian Math437 Notes January 15, 016 3 Continuous Random Variables Remember that discrete random variables can take only a countable number of possible values. On the other hand, a continuous random
More information1 Introduction and main results
A necessary and sufficient condition for the subexponentiality of product convolution Hui Xu Fengyang Cheng Yuebao Wang Dongya Cheng School of Mathematical Sciences, Soochow University, Suzhou 215006,
More informationPrecise Large Deviations for Sums of Negatively Dependent Random Variables with Common Long-Tailed Distributions
This article was downloaded by: [University of Aegean] On: 19 May 2013, At: 11:54 Publisher: Taylor & Francis Informa Ltd Registered in England and Wales Registered Number: 1072954 Registered office: Mortimer
More informationPAijpam.eu ADAPTIVE K-S TESTS FOR WHITE NOISE IN THE FREQUENCY DOMAIN Hossein Arsham University of Baltimore Baltimore, MD 21201, USA
International Journal of Pure and Applied Mathematics Volume 82 No. 4 2013, 521-529 ISSN: 1311-8080 (printed version); ISSN: 1314-3395 (on-line version) url: http://www.ijpam.eu doi: http://dx.doi.org/10.12732/ijpam.v82i4.2
More informationOn Optimal Stopping Problems with Power Function of Lévy Processes
On Optimal Stopping Problems with Power Function of Lévy Processes Budhi Arta Surya Department of Mathematics University of Utrecht 31 August 2006 This talk is based on the joint paper with A.E. Kyprianou:
More informationCompetitive Equilibria in a Comonotone Market
Competitive Equilibria in a Comonotone Market 1/51 Competitive Equilibria in a Comonotone Market Ruodu Wang http://sas.uwaterloo.ca/ wang Department of Statistics and Actuarial Science University of Waterloo
More informationProbability and Measure
Chapter 4 Probability and Measure 4.1 Introduction In this chapter we will examine probability theory from the measure theoretic perspective. The realisation that measure theory is the foundation of probability
More information