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Research article

On the improved thinning risk model under a periodic dividend barrier strategy

  • Received: 14 April 2021 Accepted: 14 September 2021 Published: 18 September 2021
  • MSC : 91B30, 97M30

  • In this study, we consider a periodic dividend barrier strategy in an improved thinning risk model, which indicates that insurance companies randomly receive premiums and pay dividends. In the improved model, the premium is stochastic, and the claim counting process is a p-thinning process of the premium counting process. The integral equations satisfied by the Gerber-Shiu function and the expected discounted cumulative dividend function are derived. Explicit expressions of those actuarial functions are obtained when the claim and premium sizes are exponentially distributed. We analyze and illustrate the impact of various parameters on them and obtain the optimal barrier. Finally, a conclusion is drawn.

    Citation: Fuyun Sun, Yuelei Li. On the improved thinning risk model under a periodic dividend barrier strategy[J]. AIMS Mathematics, 2021, 6(12): 13448-13463. doi: 10.3934/math.2021779

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  • In this study, we consider a periodic dividend barrier strategy in an improved thinning risk model, which indicates that insurance companies randomly receive premiums and pay dividends. In the improved model, the premium is stochastic, and the claim counting process is a p-thinning process of the premium counting process. The integral equations satisfied by the Gerber-Shiu function and the expected discounted cumulative dividend function are derived. Explicit expressions of those actuarial functions are obtained when the claim and premium sizes are exponentially distributed. We analyze and illustrate the impact of various parameters on them and obtain the optimal barrier. Finally, a conclusion is drawn.



    In insurance companies, the premium income is collected through insurance policies at discrete times, and each claim comes from the received policies, where the size of a claim for each policy is random. Therefore, we consider a thinning risk model in which the premium income of an insurance company is not a deterministic function of time (i.e. linear drift, see, e.g., [1,2]) but a stochastic process.

    In resent years, Boikov [3] studied the Cramér-Lundberg model where the premium process is stochastic. References [4,5] considered a risk model where both the premium process and claim process are compound Poisson processes. Further, Albrecher and Boxma [6] considered a dependent setting between claim sizes and claim intervals in a generalization of the classical risk model. Wang and Yuen [7] studied a thinning dependence structure with n(n2) dependent classes of insurance business. Moreover, numerous dependence structures have been studied, see e.g. [8,9,10,11], and so on. Inspired by the dependence of the premiums and claim amounts in the actual environment, we consider that the premium process is a thinning process of the claim process.

    With increases in the standard of living, insurance awareness has improved rapidly, leading to fierce competition among insurance companies. To attract more investors, insurance companies have proposed a dividend plan. Dividend strategy was first introduced into a risk model by reference [12]. The most common dividend payment strategies are the barrier strategy and the threshold strategy [13]. Under the barrier strategy, any excess over a fixed barrier level is paid out immediately. Under the threshold strategy, the dividend is paid out at a constant rate whenever the surplus is above a pre-specified threshold level. Under these strategies, dividend decisions are assumed to be continuous. However, references [10,14] proposed randomized observations, where dividend decisions are not continuous but are discrete only at "observation time points", which is more realistic. At these points, any excess over a fixed barrier level is paid as a dividend. Some recent papers on periodic dividend strategy can be found in references [15,16,17,18,19,20,21,22].

    Motivated by those works above, we consider the model with to combine the thinning process and the periodic dividend strategy into a risk model.} Given a probability space (Ω,F,P) satisfying the usual conditions and complete filtration {Ft,t0}. Let u0 be the initial capital of an insurance company. Without any dividend strategies, the surplus of the insurance company at time t has the form

    R(t)=u+P(t)S(t),u0,t0, (1.1)

    where P(t)=N(t)i=1Yi represents the total premium amount up to time t, and S(t)=Np(t)i=1Xi represents the aggregate claim amount up to time t. {N(t),t0} is a homogeneous Poisson process with parameter λ>0, which is a counting process that represents the number of premiums up to time t; {Np(t),t0} is the thinning process of N with parameter λp(0<p<1), which is a counting process that represents the number of claims up to time t; X1,X2, are positive i.i.d. random variables with common distribution function F(x), where Xi denotes the ith claim size; Y1,Y2, are positive i.i.d. random variables with common distribution function G(y), where Yi denotes the ith premium size. We assume that {N(t),t0}, {Xi}i=1, and {Yi}i=1 are independent of each other. Without loss of generality, we assume the safety loading condition EP(t)>ES(t). Denote the total amount of dividends up to time t by D(t). Then the final risk model is given by

    U(t)=u+P(t)S(t)D(t),t0,u0. (1.2)

    Let Tu,b=inf{t>0:U(t)<0} be the time of ruin of risk model (1.2).

    For dividends, specifically, we consider such a randomized dividend strategy with a fixed barrier level b>0 and exponential inter-dividend-decision times τ1, τ2, (τ1<τ2<) with the parameter r>0. Without loss of generality, let τ0=0 and note that τ0=0 is not a dividend decision time. Then the total amount of dividends up to time t is

    D(t)=t0(U(s)b)+dNr(s),t0,

    where {Nr(t),t0} is a homogeneous Poisson process with parameter r and it is independent of (X,Y,N,Np); (x)+=x if x0 and otherwise when x<0, (x)+=0; f(x0±) means the right (left) hand limit at the point x=x0.

    The first question to consider is the expected discounted penalty function, which was first introduced by reference [23]. Because the Gerber-Shiu function provides a comprehensive mathematical tool for studying some related quantities of ruin, such as the ultimate ruin probability, the Laplace transform of the ruin time, the deficit at ruin, the surplus immediately prior to ruin, and so on. Therefore, since it was proposed, it has been studied in various risk models [24,25,26,27,28,29,30]. It continues to be a popular topic. Now we define the Gerber-Shiu function as follows:

    mb(u)=E[eδTu,bω(U(Tu,b),|U(Tu,b)|)I{Tu,b<+}|U(0)=u], (1.3)

    where δ0 is a constant discount factor; ω(x,y) is a non-negative function with x,y0, which can be interpreted as the penalty function of the surplus immediately prior to ruin U(Tu,b) and the deficit at ruin |U(Tu,b)|; and I{A} is the indicator function. For convenience, we use the notation mb(u)Eu[eδTu,bω(U(Tu,b),|U(Tu,b)|) I{Tu,b<+}] to denote the above conditional expectation. When ω(x,y)=1, we denote mb(u)ϕb(u); When ω(x,y)=y, we denote mb(u)ξb(u).

    The second question we consider is the expected discounted cumulative dividend function, which is given by

    Vb(u)=Eu[k=1eδTk(U(Tk)b)+I{Tk<Tu,b}],u0, (1.4)

    where Tk=ki=0τi, k1, represents the kth dividend decision time.

    The rest of the paper is organized as follows: We obtain the integral equations satisfied by mb(u) and Vb(u), and prove the continuity of mb(u) and Vb(u) in Section 2. When the claim and premium sizes are exponentially distributed, the explicit expressions for mb(u) and Vb(u) are derived in Section 3. Furthermore, we conclude that in Section 3 both mb(u) and Vb(u) are discontinuous at u=b. In Section 4 we present the graphs of the Laplace transform of the deficit at ruin ξb(u), the Laplace transform of the time of ruin ϕb(u), and Vb(u). Finally, Section 5 provides the conclusions.

    Theorem 1. We denote mb(u)=mb1(u) for 0u<b, and mb(u)=mb2(u) for ub. Then the Gerber-Shiu function mb(u), u>0, satisfies the following integral equations:

    (λ+δ)mb1(u)λpbu0u+y0mb1(u+yx)dF(x)dG(y)λpbu(u+yu+ybmb1(u+yx)dF(x)+u+yb0mb2(u+yx)dF(x))dG(y)λ(1p)(bu0mb1(u+y)dG(y)+bumb2(u+y)dG(y))λp0u+yω(u+y,xuy)dF(x)dG(y)=0,0u<b, (2.1)
    (λ+δ+r)mb2(u)λ(1p)0mb2(u+y)dG(y)rmb2(b)λp0(u+yu+ybmb1(u+yx)dF(x)+u+yb0mb2(u+yx)dF(x))dG(y)λp0u+yω(u+y,xuy)dF(x)G(y)=0,ub, (2.2)

    with the continuity condition

    mb1(b)=mb2(b). (2.3)

    Proof of Theorem 1. Note that it is intuitive that the surplus process U well defined in (1.2) has the strong Markov property, though the formal verification of this fact may prove tedious. The prove is omitted here. For convenience, we denote Hu,b=eδTu,bω(U(Tu,b),|U(Tu,b)|)I{Tu,b<+}, then mb(u)=Eu[Hu,b].

    Let li denote the ith premium arrival time and let mi denote the ith claim arrival time, i1,iN. In an infinitesimal time interval [0,t], the event {l1>t} denotes that there is no income in the time interval [0,t], the event {m1>t} denotes that there is no claim, the event {τ1>t} denotes that there is no observation, that means there is no paid, similarly. According to the assumption of independence of {N(t),t0}, {Nr(t),t0}, {Yi}i=1, and {Xi}i=1 and dependence of {N(t),t0} and {Np(t),t0}, we consider four possible events in time interval [0,t]:

    1.No income, no claim, and no observation;

    2.No income, no claim, but an observation time occurs;

    3.One-time income, no claim, and no observation;

    4.One-time income, one-time claim, and no observation.

    The probability of other events is o(t), which is equal to 0 as t tends to 0.

    Using the total probability formula, we have

    mb(u)=Eu[Hu,b,l1>t,m1>t,τ1>t]+Eu[Hu,b,l1>t,m1>t,τ1<t<τ2]+Eu[Hu,b,l1<t<l2,m1>t,τ1>t]+Eu[Hu,b,l1<t<l2,m1<t<m2,τ1>t]+o(t)I1+I2+I3+I4+o(t). (2.4)

    From the double conditional expectation theorem, the above assumptions, and the strong Markov property, we obtain

    I1=E[Eu[Hu,b,l1>t,m1>t,τ1>t|ϝt]]=E[l1>t,m1>t,τ1>t,eδtmb(U(t))]=P(l1>t,m1>t)P(τ1>t)eδtmb1(u)=e(λ+r+δ)tmb1(u),I2=E[Eu[Hu,b,l1>t,m1>t,τ1<t<τ2|ϝt]]=E[l1>t,m1>t,τ1<t<τ2,eδtmb(u)]=P(l1>t,m1>t)P(τ1<t<τ2)mb1(u)=e(λ+δ)t(1ert)mb1(u),I3=E[Eu[Hu,b,l1<t<l2,m1>t,τ1>t|ϝt]]=E[l1<t<l2,m1>t,τ1>t,eδtmb(u+Y)]=P(τ1>t)P(l1<t<l2,m1>t)eδtE[mb(u+Y)]=e(r+δ)tt0P(m1>l|l1=l)λeλldlE[mb(u+Y)]=e(r+δ)t(1p)(1eλt)[bu0mb1(u+y)dG(y)+bumb2(u+y)dG(y)],I4=E[Eu[Hu,b,l1<t<l2,m1<t<m2,τ1>t|ϝt]]=E[l1<t<l2,m1<t<m2,τ1>t,eδtmb(u+YX)]=eδtP(τ1>t)P(l1<t<l2,m1<t<m2)E[mb(u+YX)]=e(r+δ)tt0P(m1=l|l1=l)λeλldlE[mb(u+YX)]=e(r+δ)tp(1eλt)[bu0u+y0mb1(u+yx)dF(x)dG(y)+bu(u+yu+ybmb1(u+yx)dF(x)+u+yb0mb2(u+yx)dF(x))dG(y)+0u+yω(u+y,xuy)dF(x)dG(y)].

    Using Taylor's theorem, we derive

    I1=[1(λ+r+δ)t]mb1(u)+o(t), (2.5)
    I2=rtmb1(u)+o(t), (2.6)
    I3=λ(1p)t[bu0mb1(u+y)dG(y)+bumb2(u+y)dG(y)]+o(t), (2.7)
    I4=λpt[bu0u+y0mb1(u+yx)dF(x)dG(y)+0u+yω(u+y,xuy)dF(x)dG(y)+bu(u+yu+ybmb1(u+yx)dF(x)+u+yb0mb2(u+yx)dF(x))dG(y)]+o(t). (2.8)

    Thus,

    limt0I1mb1(u)t=(λ+r+δ)mb1(u),limt0I2t=rmb1(u),limt0I3t=λ(1p)[bu0mb1(u+y)dG(y)+bumb2(u+y)dG(y)],limt0I4t=λp[bu0u+y0mb1(u+yx)dF(x)dG(y)+0u+yω(u+y,xuy)dF(x)dG(y)+bu(u+yu+ybmb1(u+yx)dF(x)+u+yb0mb2(u+yx)dF(x))dG(y)].

    Substituting Eqs (2.5)(2.8) into Eq (2.4), and rewriting it in a more visible way. Thus Eq (2.1) can be obtained by dividing t both sides as well as considering that t tends to 0.

    When ub, we can obtain Eq (2.2) by using similar methods.

    The continuity condition (2.3) can be obtained easily by letting u tend to b in Eqs (2.1) and (2.2).

    Theorem 2. We denote Vb(u)=Vb1(u) for 0u<b, and Vb(u)=Vb2(u) for ub. Then the expected discounted cumulative dividend function Vb(u), u>0, satisfies the following integral equations:

    (λ+δ)Vb1(u)λpbu0u+y0Vb1(u+yx)dF(x)dG(y)λpbu(u+yu+ybVb1(u+yx)dF(x)+u+yb0Vb2(u+yx)dF(x))dG(y)λ(1p)(bu0Vb1(u+y)dG(y)+buVb2(u+y)dG(y))=0,0u<b, (2.9)
    (λ+δ+r)Vb2(u)λ(1p)0Vb2(u+y)dG(y)r(ub+Vb2(b))λp0(u+yu+ybVb1(u+yx)dF(x)+u+yb0Vb2(u+yx)dF(x))dG(y)=0,ub, (2.10)

    with the continuity condition

    Vb1(b)=Vb2(b). (2.11)

    Proof of Theorem 2. The method of this proof is similar to Theorem 1, which is omitted here.

    Remark 3. When r (i.e. periodic dividend strategy evolved into continuous dividend strategy), our results are consistent with [8].

    Remark 4. When r0, which means the expectation of the first dividend decision time tends to infinity, then in this case Vb(u)0 (i.e. no dividends).

    Since it is difficult to solve Eqs (2.1), (2.2), (2.9) and (2.10), in this section, both claim sizes and premium sizes are assumed to be independent, exponentially distributed random variables. Specifically, let F(x)=1eax, G(y)=1emy, a>0, m>0, and the net profit condition a>mp. We give the closed-form expressions of Gerber-Shiu function mb(u), u>0 and the expected discounted cumulative dividend function Vb(u), u>0.

    In this subsection, we assume that ω(x,y)=y. Then in this case mb(u)ξb(u) denotes the Laplace transform of the deficit at ruin. Its explicit expressions under these assumptions are given as follows.

    Let z=u+y in Eqs (2.1) and (2.2), so that they can be simplified as

    (λ+δ)ξb1(u)=λ(1p)memu(buξb1(z)emzdz+bξb2(z)emzdz)+λpamemub(zzbξb1(zx)e(ax+mz)dx+zb0ξb2(zx)e(ax+mz)dx)dz+λpamemubuz0ξb1(zx)e(ax+mz)dxdz+λmpeaua(a+m),0u<b, (3.1)
    (λ+δ+r)ξb2(u)=λ(1p)memuuξb2(z)emzdz+λmpeaua(a+m)+rξb2(b+)+λpamemub(zzbξb1(zx)e(ax+mz)dx+zb0ξb2(zx)e(ax+mz)dx)dz,ub. (3.2)

    By differentiating both sides of (3.1) and (3.2) with respect to u, we obtain

    (λ+δ)ξb1(u)=λ(1p)m2emu(buξb1(z)emzdz+bξb2(z)emzdz)+λpam2emub(zzbξb1(zx)e(ax+mz)dx+zb0ξb2(zx)e(ax+mz)dx)dz+λpam2emubuz0ξb1(zx)e(ax+mz)dxdzλmpeaua+mλ(1p)mξb1(u)λpmau0ξb1(ux)eaxdx,0u<b, (3.3)
    (λ+δ+r)ξb2(u)=λ(1p)m2emuuξb2(z)emzdzλmpeaua+m+λpam2emuu(zzbξb1(zx)e(ax+mz)dx+zb0ξb2(zx)e(ax+mz)dx)dzλ(1p)mξb2(u),ub. (3.4)

    By differentiating both sides of (3.3) and (3.4) with respect to u, we have

    (λ+δ)ξb1(u)=λ(1p)m3emu(buξb1(z)emzdz+bξb2(z)emzdz)+λpam3emubuz0ξb1(zx)e(ax+mz)dxdz+λpameaua+m+λpam3emub(zzbξb1(zx)e(ax+mz)dx+zb0ξb2(zx)e(ax+mz)dx)dz+(am)λpmau0ξb1(ux)eaxdxλ(1p)mξb1(u)λ(1p)m2ξb1(u)λpamξb1(u),0u<b, (3.5)
    (λ+δ+r)ξb2(u)=λ(1p)m3emuuξb2(z)emzdz+aλmpeaua+m+λpam3emub(zzbξb1(zx)e(ax+mz)dx+zb0ξb2(zx)e(ax+mz)dx)dz+(am)λpma(uubξb1(ux)eaxdx+ub0ξb2(ux)eaxdx)λ(1p)m2ξb2(u)λ(1p)mξb2(u)λpamξb2(u),ub. (3.6)

    Calculating (3.3)m×(3.1) and (3.5)m×(3.3), we obtain

    (λ+δ)ξb1(u)m(λp+δ)ξb1(u)+λpm(eau+au0ξb1(ux)eaxdx)=0. (3.7)
    (λ+δ)ξb1(u)m(λp+δ)ξb1(u)+λpamξb1(u)λpma(eau+au0ξb1(ux)eaxdx)=0. (3.8)

    Calculating (3.8)+a×(3.7) and rearranging, the following second-order homogeneous ordinary differential equation (ODE) is derived:

    (λ+δ)ξb1(u)+[a(λ+δ)m(λp+δ)]ξb1(u)amδξb1(u)=0. (3.9)

    Calculating (3.4)m×(3.2) and (3.6)m×(3.4) yields

    (λ+δ+r)ξb2(u)m(λp+δ+r)ξb2(u)+λpmeau+mrξb2(b+)+λpma(uubξb1(ux)eaxdx+ub0ξb2(ux)eaxdx)=0. (3.10)
    (λ+δ+r)ξb2(u)m(λp+δ+r)ξb2(u)λpmaeau+λpamξb2(u)λpma2(uubξb1(ux)eaxdx+ub0ξb2(ux)eaxdx)=0. (3.11)

    Calculating (3.11)+a×(3.10) and rearranging, we obtain the following second-order nonhomogeneous ODE:

    (λ+δ+r)ξb2(u)+[a(λ+δ+r)m(λp+δ+r)]ξb2(u)am(δ+r)ξb2(u)+amrξb2(b+)=0. (3.12)

    The general solution to Eq (3.9) is obtained as follows:

    ξb1(u)=A1es1u+A2es2u,0u<b, (3.13)

    where s1<0, s20 are the roots of the characteristic equation (λ+δ)s2+[a(λ+δ)m(λp+δ)]samδ=0; and A1, A2 are the undetermined coefficients.

    The general solution of Eq (3.12) has the form

    ξb2(u)=A3es3u+A4es4u+rr+δξb2(b+),ub, (3.14)

    where s3<0, s40 are the roots of the characteristic equation (λ+δ+r)s2+[a(λ+δ+r)m(λp+δ+r)]sam(δ+r)=0; A3, A4 are the undetermined coefficients; and rr+δξb2(b+) is a special solution of Eq (3.12).

    By substituting (3.13) into (3.7), we see that (3.13) satisfies (3.7) only if

    a2(s2+a)A1+a2(s1+a)A2=(s1+a)(s2+a). (3.15)

    From the continuity condition (2.3), we have ξb1(b)=ξb2(b+). From the formulae (3.3) and (3.4), we have (λ+δ)ξb1(b)=(λ+δ+r)ξb2(b+). Then

    δes1bA1+δes2bA2(δ+r)es3bA3(δ+r)es4bA4=0, (3.16)
    (λ+δ)(es1bs1A1+es2bs2A2)(λ+δ+r)(es3bs3A3+es4bs4A4)=0. (3.17)

    By substituting (3.13) and (3.14) into (3.1), we see that (3.13) and (3.14) satisfy (3.1) only if

    l1es1bA1+l2es2bA2l3es3bA3l4es4bA4=0, (3.18)

    where

    l1=[r(1p)r+δ+paa+m(ma+s1+rr+δ)mms1(1p+paa+s1),l2=r(1p)r+δ+paa+m(ma+s2+rr+δ)mms2(1p+paa+s2),l3=mms3(1p+paa+m),l4=mms4(1p+paa+m).

    Let

    w1=δ(λ+δ+r)(l4s3l3s4)+(δ+r)[(λ+δ+r)(s4s3)l2(λ+δ)(l4l3)s2],w2=δ(λ+δ+r)(l3s4l4s3)+(δ+r)[(λ+δ)(l4l1)s1(λ+δ+r)(s4s3)l1],w3=δ[(λ+δ)(s1s2)l4+(λ+δ+r)(l2l1)s4](δ+r)(λ+δ)(l2s1l1s2),w4=δ[(λ+δ)(s1s2)l3+(λ+δ+r)(l2l1)s3](δ+r)(λ+δ)(l2s1l1s2),w5=(λ+δ+r)(s4s3)(l2l1)+(λ+δ)[(l4l1)s1(l4l3)s2].

    Solving the system of Eqs (3.15)(3.18), we can obtain A1A4. Then we have

    ξb(u)={(s1+a)(s2+a)[w1e(s2b+s1u)+w2e(s1b+s2u)]a2[(s2+a)w1es2b+(s1+a)w2es1b],0u<b,(s1+a)(s2+a)e(s1+s2)b[rw5+w3e(s4b+s3u)w4e(s3b+s4u)]a2e(s3+s4)b[(s2+a)w1es2b+(s1+a)w2es1b],ub.

    In this subsection, we assume ω(x,y)=1. Then in this case mb(u)ϕb(u) denotes the Laplace transform of the ruin time. The explicit expressions of ϕb(u) under the above assumptions are given as follows:

    Using the same method as in the previous section, we obtain

    (λ+δ)ϕb1(u)+[a(λ+δ)m(λp+δ)]ϕb1(u)amδϕb1(u)=0, (3.19)

    and

    (λ+δ+r)ϕb2(u)+[a(λ+δ+r)m(λp+δ+r)]ϕb2(u)am(δ+r)ϕb2(u)+amrϕb2(b+)=0. (3.20)

    The explicit expressions for the Laplace transform of the ruin time can be obtained from the following equations:

    a(s2+a)B1+a(s1+a)B2=(s1+a)(s2+a), (3.21)
    δes1bB1+δes2bB2(δ+r)es3bB3(δ+r)es4bB4=0, (3.22)
    (λ+δ)(es1bs1B1+es2bs2B2)(λ+δ+r)(es3bs3B3+es4bs4B4)=0, (3.23)

    and

    l1es1bB1+l2es2bB2l3es3bB3l4es4bB4=0, (3.24)

    where li, si, i=1,2,3,4 are the same as in Section 3.1; and the undetermined coefficients B1B4 can be easily obtained from (3.21)(3.24). Then we have

    ϕb(u)={(s1+a)(s2+a)[w1e(s2b+s1u)+w2e(s1b+s2u)]a[(s2+a)w1es2b+(s1+a)w2es1b],0u<b,(s1+a)(s2+a)e(s1+s2)b[rw5+w3e(s4b+s3u)w4e(s3b+s4u)]ae(s3+s4)b[(s2+a)w1es2b+(s1+a)w2es1b],ub.

    In this subsection, we provide the explicit expression of Vb(u),u>0, by using the same method as in Section 3.1. Similar to (3.19)(3.24), we have

    (λ+δ)Vb1(u)+[a(λ+δ)m(δ+λ+mp)]Vb1(u)amδVb1(u)=0, (3.25)

    and

    (λ+δ+r)Vb2(u)+[a(r+λ+δ)m(r+δ+λp)]Vb2(u)am(δ+r)Vb2(u)+amr(ub+Vb2(b+))=0, (3.26)

    The explicit expressions can be obtained from the following equations:

    1s1+aC1+1s2+aC2=0, (3.27)
    δes1bC1+δes2bC2(δ+r)es3bC3=r[a(r+λ+δ)m(r+δ+λp)]am(r+δ), (3.28)
    (λ+δ)(es1bs1C1+es2bs2C2)(λ+δ+r)es3bs3=rλr+δ, (3.29)

    where s1s3 are the same as in Section 3.1; and the undetermined coefficients C1C3 can be easily obtained from (3.27)(3.29).

    Let

    w6=[a(r+λ+δ)m(r+δ+λp)](r+λ+δ)s3λam(r+δ),w7=(s2+a)[(λ+δ)(r+δ)s2δ(r+λ+δ)s3]es2b(s1+a)[(λ+δ)(r+δ)s1δ(r+λ+δ)s3]es1b,w8=λamrδ(r+δ)[(s2+a)es2b+(s1+a)es1b]r(λ+δ)[a(r+λ+δ)m(r+δ+λp)][(s2+a)s2es2b+(s1+a)s1es1b].

    Then we have

    Vb(u)={rw6[(s1+a)es1u+(s2+a)es2u]am(r+δ)w7,0u<b,r2w6[(s1+a)es1b+(s2+a)es2b]+(r+δ)w8es3(ub)am(r+δ)2w7+r[am(r+δ)(ub)+a(r+λ+δ)m(r+δ+λp)]am(r+δ)2,ub.

    In this section, we respectively reveal the impact of various parameters on the Laplace transform of the deficit at ruin, the Laplace transform of the ruin time, and the expected discounted cumulative dividend function. In order to investigate that, in the following analysis, unless otherwise specified, the basic parameter settings are as follows: λ=1, p=0.2, b=2, u=1, r=0.05, a=1, m=1, δ=0.05.

    In this subsection, we examine the impact of each parameter on the Laplace transform of the deficit at ruin ξb(u) to study its sensitivity. According to the sensitivity, we can control the deficit at ruin by adjusting the parameters of different insurance products.

    In Figure 1, we respectively present the graphs of the Laplace transform of the deficit at ruin ξb(u) for three different values of λ, p, a, m, r, and δ.

    Figure 1.  The curves of Laplace transform of the deficit at ruin ξb(u) as a function of u when: (a) λ=1,2,4; (b) p=0.2,0.4,0.6; (c) a=2,3,4; (d) m=0.5,1,1.5; (e) r=0.05,0.25,0.45; (f) δ=0.01,0.03,0.05.

    From Figure 1, we can see the following conclusions:

    (1) Figure 1(a) shows that the Laplace transform of the deficit at ruin ξb(u) increases with respect to the Poisson parameter λ of the premium counting process {N(t),t>0}. Note that parameter λ denotes the average incidence of random events per unit time. An increase of λ means that the number of premium policies and claims occurred increases in the unit area. Figure 1(a) shows that the more premiums collected per unit of time, the greater the liabilities arising from bankruptcy, which is consistent with our intuitive understanding.

    (2) From Figure 1(b) we see that as p increases, ξb(u) increases. This phenomenon is because that the number of claims generated increases when p increases. For insurance companies, different values of p can represent different insurance products.

    (3) ξb(u) is decreasing with respect to a and δ, respectively, see Figure 1(c), (f). The parameter δ is the discount rate, which is easy to understand. An increase in a leads to a decrease in cost for the insurance company, which makes bankruptcy happen earlier.

    (4) As is seen from Figure 1(d), ξb(u) is a monotonic increasing function of m. Increased m causes an increase in the insurance company's revenue, which makes bankruptcy occur later.

    (5) Figure 1(e) shows that ξb(u) is increasing with respect to r. Dividends are equivalent to the expenses of the insurance company. The larger r is, the more dividends paid out per unit of time, which means the higher costs for insurance companies. We can control the deficit by appropriately reducing the value of r.

    In this subsection, we depict the effects of various parameters on the Laplace transform of ruin time ϕb(u). In applications, it is reasonable that the shareholders of the company are interested in ϕb(u) for that they can avoid ruin by adjusting the values of parameters.

    In Figure 2, we present the graphs of the Laplace transform of the ruin time ϕb(u) as the functions of (λ,p)[1,4]×(0,1); (m,a)(0,1]×[2,3]; (u,b)[0,1]×[0,1], respectively.

    Figure 2.  Laplace transform of the time of ruin ϕb(u) as functions of (a) λ and p; (b) m and a; (c) u and b.

    From these graphs, we obtain some results as follows:

    (1) ϕb(u) is decreasing in u, and b, respectively. The initial capital u has a significant impact on the ruin time: A high initial capital can curb bankruptcy. An increase of b means a reduction in the payment of dividends per time, that is, a lower cost of insurance companies, which leads to that ruin occurs later.

    (2) ϕb(u) decreases with respect to a and increases with respect to λ, p, and m, respectively. The interpretation is similar to that of the previous one. We omitted here.

    In this subsection, we depict the effects of the parameters u and b on the expected discounted cumulative dividend function Vb(u).

    From Figure 3(a), we can see that Vb(u) is increasing in the initial capital u, which is obvious and easy to understand. However, from Figure 3(b), it can be seen that Vb(u) is decreasing in the dividend barrier b. For fixed initial capital u, the maximum value is V0(u), then we have that the optimal barrier b=0. We also conclude that the optimal barrier b is independent of the initial capital u. From Figure 3(c), we have Vb(u)=0 when r0. This verifies the result of Remark 4.

    Figure 3.  The value of Vb(u) as functions of (a) u when b=2,3,4 and (b) b when u=3,4,5 and (c) r when u=1,b=2 and u=3,b=2, respectively.

    In this paper, we consider an improved thinning risk model with a periodic barrier strategy. This improved risk model is of great practical significance since it is much closer to the actual operate model of insurance companies. We examined the expected discounted penalty function mb(u) and the expected discounted cumulative dividend function Vb(u) under the assumption that inter-dividend-decision times is subject to exponential distribution. Not only the integral equation satisfied by them are obtained, but the explicit expressions for them are derived by means of the integral and differential method when the claim amount and premium sizes are exponentially distributed. Finally, by some numerical analysis, we conclude some results that can be used to risk management of insurance companies. In the end, we find Vb(u) is decreasing in b and that the optimal barrier b=0.

    For the further research, diffusion could be considered in this thinning model. In addition, we can also consider the inter-dividend-decision times following Erlang(n) distribution.

    The authors would like to thank to Profs. Yuhua Lv, Chuancun Yin, and Zhanjie Song for their useful suggestions, which improved an earlier version of the paper. The authors thank as well the two anonymous referees and editor for their helpful comments and suggestions. The research was supported by the National Natural Science Foundation of China (No.12071251).

    All authors declare no conflicts of interest in this paper.



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