This paper develops a probabilistic decomposition method for an Mξ/G/1 repairable queueing system with multiple vacations, in which the customers who arrive during server vacations enter the system with probability p. Such a novel method is used to analyze the main performance indices of the server, such as the unavailability and the mean failure number during (0,t]. It is derived that the structures of server indices are two convolution equations. Further, comparisons with existing methods indicate that our method is effective and applicable for studying server performances in single-server Mξ/G/1 vacation queues and their complex variants. Finally, a stochastic order and production system with a multipurpose production facility is numerically presented for illustrative purpose.
1. Introduction
There are some effective and convenient analytic methods for single-server queues with a repairable server or service station. For example, the Markov renewal process method is used to study an M/G/1 queueing system with repairable service station in [1], the geometric process method introduced by Lam is applied to analyze the lifetime behaviors and repair times of deteriorating service station in [2, 3], and the matrix-geometric method is available for GI/M/1 and M/Ek/1 repairable queues in [4, 5]. It is well known that the supplementary variable method posed by Cox [6] is very important in dealing with some Poisson input queues with a repairable server. Many researchers, such as Wang [7], Ke et al. [8], Liu et al. [9], and Cao [10], have utilized this method for lots of repairable single-server queueing systems. The above approaches were applied to analyze some queueing indices, such as queue size, waiting time, and their stochastic decompositions, and the performance measures of the server, such as the mean times to the first failure, unavailability and failure frequency. However, the common methods mentioned above usually become too complicated to be solved especially when dealing with some Poisson input bulk arrival queues with a repairable server and their complex vacation variants.
In this paper, based on the renewal process theory and Laplace and Laplace-Stieltjes transforms we develop a probabilistic decomposition method to analyze the performance measures of the repairable server for a single-server Mξ/G/1 queue with variable input rate and multiple vacations. Our method is completely different from the methods used in [1–10] and reveals that the structures of the server indices in Poisson input single-server bulk arrival vacation queues are two convolution equations. Our analytic idea is presented as follows: (1) with the definition of “generalized server busy period”, we get the conditional probability that the time t is during the generalized server busy period; (2) according to this probability and our probabilistic decomposition method, we obtain the unavailability and average failure number of the server, which derive two convolution equations; (3) finally, by means of a special case, comparisons are made between our new method and supplementary variable method. Comparisons indicate that our method is more effective and applicable for Poisson input single-server bulk arrival queues with a repairable server and their complex vacation variants.
The rest of the paper is organized as follows. Sections 2 and 3 give the queue assumptions and preliminaries, respectively. In Section 4 a probabilistic decomposition method is developed to analyze main server indices. A special case is presented to validate our results and make comparisons between our new method and supplementary variable method. In Section 5 as a real world example we numerically analyze the influences of system parameters on main facility indices for a stochastic order and production system with a multi-purpose production facility. Conclusions are finally drawn in Section 6.
2. Assumptions
we consider an Mξ/G/1 vacation queueing system with variable input rate as follows.
The interarrival times between batch customers, {τi,i≥1}, are independent identically distributed (i.i.d) random variables with distribution function F(t)=1-e-λt, t≥0. Each batch size ξ is a random variable following distribution P(ξ=k)=ek, k≥1 with finite mean e and probability-generating function (PGF) A(z)=∑k=1∞ekzk,|z|<1.
The service order for customers in different batch arrivals is under the rule of FCFS, and the order in one batch arrival is arbitrary. The server can serve only one customer at a time. The service times {χn,n≥1} are i.i.d random variables each with arbitrary distribution G(t), t≥0 with finite mean μ.
The server takes multiple vacations when the system becomes empty. Let Vn be the server's the nth vacation time. Assume that Vn, n≥1 are i.i.d random variables with distribution function V(t), t≥0 and finite mean E(V). The customers who arrive during server vacations enter the system with probability p(0<p<1) or lose with probability 1-p. Upon returning from a vacation, the server immediately serves one by one when there is a waiting queue or leaves for another vacation when there is an empty queue.
The server consists of r unreliable units; these units may possibly fail if and only if the server is serving a customer. Once a unit fails, the server breaks down and cannot continue to serve. The failed unit will be repaired immediately. After the repair is completed, the server resumes operating and continues to serve the customer whose service has not been finished yet. The service time for a customer is cumulative.
During the repair of a unit, the server cannot operate and the other units cannot fail. After repair, the unit is as good as new. The lifetime Xi of unit i of the server has an exponential distribution Xi(t)=1-e-αit, t≥0, and its repair time Yi obeys an arbitrary distribution Yi(t), t≥0 with a mean repair time βi, i=1,2,…,r.
All random variables are mutually independent. At the initial time t=0, the server begins to serve when the number of customers presented in the system N(0)>0, or the server is idle and waits for the first batch arrival when N(0)=0.
Remark 1.
Assumption (6) is practical and reasonable. But it is later proved that the steady-state performance indices of server are independent of initial state N(0)=i, i≥0.
Remark 2.
Throughout this paper, we take some notations as follows: ρ~ denotes the traffic intensity of the considered queue; N(t) is the customer number of system at time t; G(k)(t) denotes the k-fold convolution of corresponding function G(t), G(0)(t)=1; g*(s)=∫0∞e-stG(t)dt and g(s)=∫0∞e-stdG(t) denote Laplace and Laplace-Stieltjes transforms of corresponding G(t), respectively; E(X) is the mean of random variable X; P(Q) is the probability of event Q; ℜ(s) denotes the real part of complex number s.
3. Preliminaries
Let X and Y denote the lifetime and repair time of server, respectively; then for t≥0, the distribution functions of X and Y are given, respectively, by
(1)X(t)=P(X≤t)=P(min(X1,X2,…,Xr)≤t)=1-e-αt,(α=∑i=1rαi),(2)Y(t)=P(Y≤t)=∑i=1rP(min(X1,X2,…,Xr)=Xi,Y=Yi≤t)=∑i=1rP(X1>Xi,…,Xi-1>Xi,(,X2,,)Xi+1>Xi,…,Xr>Xi,Yi≤t)=∑i=1rYi(t)∫0∞P(X1>x,…,Xi-1>x,(X1,X2,…,Xr)Xi+1>x,…,Xr>x)dXi(x)=1α∑i=1rαiYi(t).
Thus, the mean repair time of server is given by
(3)β=∫0∞tdY(t)=1α∑i=1rαiβi.
Definition 3.
The “service completion time of a customer” represents the time interval from the epoch when the service for a customer begins to the epoch when the service of this customer ends, which includes possible repair times of server due to its unit failures in the process of serving this customer. Denote by χ~k the service completion time of customer k; it is obvious that χ~k, k≥1, are i.i.d. random variables.
Lemma 4 (see [<xref ref-type="bibr" rid="B1">1</xref>]).
Let G~(t)=P(χ~k≤t), k≥1, then
(4)G~(t)=∑k=0∞∫0tY(k)(t-x)(αx)kk!e-αxdG(x),t≥0,g~(s)=∫0∞e-stdG~(t)=g(s+α-αy(s)),ℜ(s)>0,E(χ~)=-dg~(s)dsdg~(s)ds|s=0=μ(1+αβ),
where g(s)=∫0∞e-stdG(t) and y(s)=∫0∞e-stdY(t).
Definition 5.
The “generalized server busy period” represents the time interval from the epoch when the service begins to the epoch when the system becomes empty, which also contains possible repair times of server due to its unit failures in the process of service.
Let b~ denote the generalized server busy period initiated with one customer and its distribution function is B~(t) with Laplace-Stieltjes transform b~(s). Similar to the discussions in an M/G/1 queue with generalization vacations [11], the following lemma holds.
Lemma 6.
If ℜ(s)>0, then b~(s) is the solution with smallest absolute value in z of the equation z=g~(s+λ-λA(z)), and
(5)E(b~)={μ(1+αβ)1-λeμ(1+αβ),ρ~<1,∞,ρ~≥1,
where ρ~=λeμ(1+αβ) denotes the traffic intensity of the considered queue.
Denote by b~〈i〉 the generalized server busy period initiated with i customers; then b~〈i〉 can be expressed as b~〈i〉=∑k=1ib~k, where b~k,1≤k≤i, are mutually independent with the same distribution function as b~. Let B~〈i〉(t)=P(b~〈i〉≤t); then we can get B~〈i〉(t)=B~(i)(t); that is, B~〈i〉(t) is the i-fold convolution of B~(t).
Definition 7.
The “system idle period” represents the time interval from the epoch when the system becomes empty to the epoch when batch customers enter the system.
Denote by Ik the kth system idle period, then by the queue assumptions, {Ik,k≥1} are independent of each other, and their distribution functions are as follows:
if N(0)=0, then
(6)Ik(t)=P(Ik≤t)={1-e-λt,k=1,1-e-λpt,k=2,3,…,t≥0,
if N(0)>0, then
(7)Ik(t)=P(Ik≤t)=1-e-λpt,k=1,2,3,…,t≥0.
4. Performance Indices of the Server
In this section, we develop a probabilistic decomposition method to analyze main performance indices of the server in the considered queue, including the conditional probability that the time t is during the generalized server busy period, the unavailability and the average failure number during (0,t]. Further, it is derived that the structures of server indices are two convolution equations. Finally, a special case is presented to validate our results and make comparisons between our method and supplementary variable method.
4.1. The Conditional Probability That the Time <inline-formula>
<mml:math xmlns:mml="http://www.w3.org/1998/Math/MathML" id="M105">
<mml:mrow>
<mml:mi>t</mml:mi></mml:mrow>
</mml:math></inline-formula> is during the Generalized Server Busy PeriodTheorem 8.
For i≥0, let Ai(t)=P (the time t is during the generalized server busy period |N(0)=i); then for ℜ(s)>0, Laplace transforms of Ai(t), i≥0 are
(8)a0*(s)=λs(s+λ){1-A(b~(s))[1-v(s)]1-v(s+λp-λpA(b~(s)))},(9)ai*(s)=1s{1-b~i(s)[1-v(s)]1-v(s+λp-λpA(b~(s)))},i≥1,
and in steady state, for system traffic intensity ρ~=λeμ(1+αβ) and i≥0, one has
(10)limt→∞Ai(t)=lims→0sai*(s)={λpeμ(1+αβ)1-λ(1-p)eμ(1+αβ),ρ~<1,1,ρ~≥1,
where b~(s) is determined by Lemma 6.
Proof.
Let sk=∑i=1kVi, lk=∑i=1kτi, k≥1, s0=l0=0, ∑n[m]=m∞=∑n1=1∞⋯∑nm=1∞, and n[m]=n1+⋯+nm. Denote by b~〈k〉 the generalized server busy period initiated with k customers with distribution function B~〈k〉(t) (see Definition 5), and Ik is the kth system idle period with distribution function Ik(t) (see Definition 7). Noting that the ending points of server vacation and generalized server busy period are renewal points, and the server takes no vacations when N(0)=0, we have
(11)A0(t)=∑k=1∞ekP(I1<t≤I1+b~〈k〉)+∑k=1∞ek∑j=1∞∑m=1∞P(sj-1<I2≤sj,ggggggggggggggggI2+lm-1<sj≤I2+lm,ggggigggggggggggt>I1+b~〈k〉+sj,(t-x)(t-x)(t-x)gthetimetisduring(t-x)(t-x)(t-x)gthe generalized(t-x)(t-x)(t-x)gserver busy period)=∑k=1∞ek∫0t[1-B~(k)(t-x)]dF(x)+∑k=1∞ek∑j=1∞∑m=1∞∑n[m]=m∞en1⋯enm×∫0t∫0t-x∫0t-x-yAn[m](t-x-y-u)(λpu)mm!×e-λp(u+y)dV(u)dV(j-1)(y)d[F(x)*B~(k)(x)],
where F(x)*B~(k)(x)=∫0xF(x-t)dB~(k)(t),x≥0.
By means of the same decomposition way, for i≥1, we get
(12)Ai(t)=P(t<b~〈i〉)+∑j=1∞∑m=1∞P(sj-1<I1≤sj,hhhhhhhhhhhhhI1+lm-1<sj≤I1+lm,hhhhhhhhhhhhht>b~〈i〉+sj,(j-1)(j-1)ggthe time t is during the(j-1)(j-1)gggeneralizedserver busy period)=1-B~(i)(t)+∑j=1∞∑m=1∞∑n[m]=m∞en1⋯enm×∫0t∫0t-x∫0t-x-yAn[m](t-x-y-u)×(λpu)mm!e-λp(u+y)dV(u)dV(j-1)(y)dB~(i)(x).
Taking Laplace transforms of (11) and (12), respectively, gives rise to
(13)a0*(s)=λs(s+λ)[1-A(b~(s))]+f(s)A(b~(s))1-v(s+λp)×∑m=1∞∑n[m]=m∞en1⋯enman[m]*(s)∫0∞e-(s+λp)t×(λpt)mm!dV(t),(14)ai*(s)=1-b~i(s)s[1-A(b~(s))]+b~i(s)1-v(s+λp)×∑m=1∞∑n[m]=m∞en1⋯enman[m]*(s)∫0∞e-(s+λp)t×(λpt)mm!dV(t),i≥1.
By checking (13) and (14), we obtain the relation
(15)ai*(s)=1s-b~i(s)[λ-s(s+λ)a0*(s)]sλA(b~(s)),i≥1.
Substituting (15) into (13) leads to (8). Equation (9) is obtained by (8) and (15). Applying Tauberian theorem [12] and L' Hospital's rule gives (10).
In order to investigate the unavailability and the failure number during (0, t] of server, we introduce a classical r-unit series repairable system [12]. For t≥0, let
(16)Φ(t)=P(the system is repaired at timet),φ*(s)=∫0∞e-stΦ(t)dt,M(t)=E(the failure number of the system during (0,t]),m(s)=∫0∞e-stdM(t).
Lemma 9 (see [<xref ref-type="bibr" rid="B12">12</xref>]).
If ℜ(s)>0, then
(17)φ*(s)=α-∑i=1rαiyi(s)s[s+α-∑i=1rαiyi(s)],m(s)=αs+α-∑i=1rαiyi(s),limt→∞Φ(t)=lims→0sφ*(s)limt→∞Φ(t)=αβ1+αβ,limt→∞M(t)t=lims→0sm(s)=α1+αβ,
where yi(s)=∫0∞e-stdYi(t), α=∑i=1rαi and β=(1/α)∑i=1rαiβi.
4.2. The Unavailability of the Server
The unavailability of the server at time t; that is, the probability that the server is repaired at time t.
Theorem 10.
Let Φi(t)=P (the server is repaired at time t|N(0)=i), i≥0; then for ℜ(s)>0, Laplace transform of Φi(t) is
(18)φi*(s)=φ*(s)[sai*(s)],i≥0,
and for system traffic intensity ρ~=λeμ(1+αβ) and i≥0, the steady-state unavailability of the server is given by
(19)limt→∞Φi(t)={λpeμαβ1-λ(1-p)eμ(1+αβ),ρ~<1αβ1+αβ,ρ~≥1,
where φ*(s), and ai*(s), i≥0 are given by Lemma 9 and Theorem 8, respectively.
Proof.
(i) According to the queue assumptions, the server is repaired at time t if and only if the time t is during one generalized server busy period, and the server is repaired at time t. Consequently, using the law of total probability and renewal process theory, we have the decomposition of Φ0(t) as follows:
(20)Φ0(t)=∑k=1∞ekP(I1<t≤I1+b~〈k〉,(t-x)gggtheserverisrepairedattimet)+∑k=1∞ek∑j=1∞∑m=1∞P(sj-1<I2≤sj,aaaaaaaaaaaaaaaaI2+lm-1<sj≤I2+lm,t>I1aaaaaaaaaaaaaaaaaa+b~〈k〉+sj,the server is repairedaaaaaaaaaaaaaaaaaat time tb~〈k〉)=∑k=1∞ek∫0tSk(t-x)dF(x)+∑k=1∞ek∑j=1∞∑m=1∞∑n[m]=m∞en1⋯enm×∫0t∫0t-x∫0t-x-yΦn[m](t-x-y-u)×(λpu)mm!e-λp(u+y)dV(u)dV(j-1)×(y)d[F(x)*B~(k)(x)],
where Sk(t)=P(0≤t<b〈k〉, the server is repaired at time t), k≥1.
Similarly, for i≥1, Φi(t) is decomposed as
(21)Φi(t)=Si(t)+∑j=1∞∑m=1∞∑n[m]=m∞en1…enm×∫0t∫0t-x∫0t-x-yΦn[m](t-x-y-u)×(λpu)mm!e-λp(u+y)dV(u)dV(j-1)(y)dB~(i)(x).
(ii) For i≥1,
(22)Si(t)=Φ(t)-∫0tΦ(t-x)dB~(i)(x),(23)∫0∞e-stSi(t)dt=φ*(s)[1-b~i(s)],
where Φ(t) and φ*(s) are determined by Lemma 9.
In reality, Φ(t) can be decomposed as
(24)Φ(t)=P(the system is repaired at time t,b~〈i〉≤t)+P(the system is repaired at time t,b~〈i〉>t)=∫0tΦ(t-x)dB~(i)(x)+Si(t),
which leads to (22) and (23).
(iii) Taking Laplace transforms of (20) and (21), respectively, and utilizing (22) and (23), we get
(25)φ0*(s)=λs+λφ*(s)[1-A(b~(s))]+λA(b~(s))(s+λ)[1-v(s+λp)]×∑m=1∞∑n[m]=m∞en1⋯enmφn[m]*(s)×∫0∞e-(s+λp)t(λpt)mm!dV(t),(26)φi*(s)=φ*(s)[1-b~i(s)]+b~i(s)1-v(s+λp)×∑m=1∞∑n[m]=m∞en1⋯enmφn[m]*(s)×∫0∞e-(s+λp)t(λpt)mm!dV(t),i≥1.
Performing similar operations in the proof of Theorem 8 on (25) and (26), we can complete the proof by Theorem 8 and Lemma 9.
4.3. The Mean Failure Number of Server During (0, <inline-formula>
<mml:math xmlns:mml="http://www.w3.org/1998/Math/MathML" id="M179">
<mml:mrow>
<mml:mi>t</mml:mi></mml:mrow>
</mml:math></inline-formula>]Theorem 11.
Let Mi(t)=E (the failure number of server during (0,t]|N(0)=i); i≥0, then for ℜ(s)>0, Laplace-Stieltjes transform of Mi(t) is
(27)mi(s)=m(s)[sai*(s)],i≥0,
and for system traffic intensity ρ~=λeμ(1+αβ) and i≥0, the steady-state failure frequency of server, that is, in steady state, the rate of occurrence of server failures, is
(28)limt→∞Mi(t)t=lims→0smi(s)={λpeμα1-λ(1-p)eμ(1+αβ),ρ~<1,α1+αβ,ρ~≥1,
where m(s) and ai*(s), i≥0, are given by Lemma 9 and Theorem 8, respectively.
Proof.
(1) For i≥1, let
(29)Hi(t)=E(0≤t<b~〈i〉,(1aa)the failure number of server during(0,t]b~〈i〉),Li(t)=E(b~〈i〉≤t,he a gthe failure number of server during(0,b~〈i〉]);
then similar to (22), we have
(30)Hi(t)+Li(t)=M(t)-∫0tM(t-x)dB~(i)(x),i≥1,
where M(t) is determined by Lemma 9.
(2) By the law of total probability and renewal process theory, M0(t) is decomposed as
(31)M0(t)=∑k=1∞ek{E(I1<t≤I1+b~〈k〉,aaaaaaaaaaaathefailurenumberofserveraaaaaaaaaaaduring(0,t])(t-x)gg+E(t>I1+b~〈k〉,aaaaaaaaaaaaaaathe failure number of serveraaaaaaaaaaaaaduring(I1,I1+b~〈k〉])}+∑k=1∞ek∑j=1∞∑m=1∞E(t>I1+b~〈k〉+sj,aaaaaaaaaaaaaaaaasj-1<I2≤sj,aaaaaaaaaaaaaaaaaaaaI2+lm-1<sj≤I2+lm,aaaaaaaaaaaaaaaaaaaathe failure number of serveraaaaaaaaaaaaaaaaaduring(I1+b~〈k〉+sj,t])=∑k=1∞ek∫0t[Hk(t-x)+Lk(t-x)]dF(x)+∑k=1∞ek∑j=1∞∑m=1∞∑n[m]=m∞(t-x)(t-x)×en1⋯enm∫0t∫0t-x∫0t-x-y(t-x)(t-x)×Mn[m](t-x-y-u)(t-x)(t-x)×(λpu)mm!e-λp(u+y)dV(u)dV(j-1)(t-x)(t-x)×(y)d[F(x)*B~(k)(x)].
Similarly, Mi(t), i≥1, are decomposed as
(32)Mi(t)=Hi(t)+Li(t)+∑j=1∞∑m=1∞∑n[m]=m∞×en1…enm∫0t∫0t-x∫0t-x-yMn[m](t-x-y-u)aaaaaaaaaaaaaaaaaaaaa×(λpu)mm!e-λp(u+y)aaaaaaaaaaaaaaaaaaaaa×dV(u)dV(j-1)(y)dB~(i)(x),aaaaaaaaaaaaaaaaaaaaaaaV(u)dV(j-1)(y)dB~(i)i≥1.
Taking Laplace-Stieltjes transforms of (31) and (32) and using (30), Theorem 8, and Lemma 9, we get (27). Equation (28) is obtained by Tauberian theorem [12], Lemma 9, and (10).
Remark 12 (a special example).
If p=1, P(ξ=1)=1, and P(Vn=0)=1, n≥1, then our model becomes an M/G/1 repairable queue with an unreliable server [10], in which the server consists of r repairable units and operates if and only if r units operate. In this case, for ρ~=λμ(1+αβ), we get
(33)limt→∞Ai(t)={λμ(1+αβ),ρ~<11,ρ~≥1,(34)limt→∞Mi(t)t={λμα,ρ~<1α1+αβ,ρ~≥1,(35)A~=1-limt→∞Φi(t)={1-λμαβ,ρ~<1,(α=∑i=1rαi,β=1α∑i=1rαiβi),11+αβ,ρ~≥1,
where A~ denotes the steady-state availability of server.
In the above results, limt→∞Mi(t)/t and A~ agree with those in [10], which are derived with the help of the supplementary variable method. However, [10], didn't obtain limt→∞Ai(t) and limt→∞Φi(t). Further, comparisons with our results indicate that using the supplementary variable method, [10] did not derive ai*(s), φi*(s) and mi(s) for arbitrary initial state N(0)=i, i>0, and arbitrary distributions G(t) and Yk(t), k=1,2,…,r.
Remark 13.
Taking Laplace and Laplace-Stieltjes inverse transforms of (18) and (27), respectively, gives rise to the following two convolution equations:(36)Φi(t)=Φ(t)*Ai(t)=∫0tΦ(t-x)dAi(x),aaaaaaaaaat≥0,i≥0,(37)Mi(t)=M(t)*Ai(t)=∫0tM(t-x)dAi(x),aaaaaaaaaat≥0,i≥0.
Since Φ(t) and M(t) are known (see Lemma 9), it is indicated from (36) and (37) that discussing the unavailability Φi(t) and the mean failure number during (0, t] of the server Mi(t) can be simplified to discussing the conditional probability Ai(t) presented in this paper. More importantly, (36) and (37) reveal the structures of the server indices, which are not derived by the supplementary variable method in [10].
Remark 14.
From (10), (19), (28), and Lemma 9, we easily obtain two steady-state relation equations as follows:
(38)limt→∞Φi(t)=limt→∞Φ(t)limt→∞Ai(t),i≥0,(39)limt→∞Mi(t)t=limt→∞M(t)tlimt→∞Ai(t),i≥0.
What is more, we see that the two steady-state results are independent of arbitrary initial state N(0)=i, i≥0, and have nothing to do with server vacations. The above relations are also new, which are not obtained by the supplementary variable method in [10].
5. Numerical Examples
Our queueing model and its theoretical results obtained can be applied to model a stochastic order and production system with a multipurpose production facility (server). In such a system, customer orders for the product arrive in batch according to a compound Poisson process with mean arrival rate λ. The distribution for each batch order size ξ is geometric with mean E(ξ)=1/θ. The production time of each unit of the product is assumed to follow the 4-stage Erlang distribution with mean μ=2. Whenever all orders are completed and no new orders arrive, the production will be stopped and the facility may be available to perform some optional jobs (vacations). The optional jobs can make profits for the system. The orders which arrive during optional jobs will enter the queue for production with probability p(0<p<1) or lose with probability 1-p. Upon completion of each optional job, the system manager checks the orders and decides whether or not to resume the major production. If at this moment the orders are empty, a decision may be made for taking another optional job to be performed. If orders occur, production restarts. Moreover, the production may be interrupted due to some unpredictable events, which occur according to a Poisson process with rate α. The interrupted production is immediately recovered with a random time obeying the 2-stage Erlang distribution with mean β=0.8. The production will continuously start when the interruption is recovered.
Tables 1–4 present several numerical results to illustrate the influences of varying system parameters on main performance measures of production facility. We consider three facility indices: the busy probability of production facility limt→∞Ai(t), the unavailability limt→∞Φi(t), and the failure frequency limt→∞Mi(t)/t. Moreover, in all the following cases, the system load value ρ~ is also discussed.
The effects of batch order rate λ on production facility indices (p=0.8, θ=0.5, μ=2, α=0.1, and β=0.8).
λ
ρ~
limt→∞Ai(t)
limt→∞Φi(t)
limt→∞Mi(t)/t
0.10
0.4320
0.3783
0.0280
0.0350
0.15
0.6480
0.5956
0.0441
0.0551
0.20
0.8640
0.8356
0.0619
0.0774
0.25
1.0800
1
0.0741
0.0926
0.30
1.2960
1
0.0741
0.0926
0.35
1.5120
1
0.0741
0.0926
The effects of batch order entering probability p during optional jobs on production facility indices (λ=0.2, θ=0.5, μ=2, α=0.1, and β=0.8).
p
ρ~
limt→∞Ai(t)
limt→∞Φi(t)
limt→∞Mi(t)/t
0.5
0.8640
0.7606
0.0563
0.0704
0.6
0.8640
0.7922
0.0587
0.0733
0.7
0.8640
0.8164
0.0605
0.0756
0.8
0.8640
0.8356
0.0619
0.0774
0.9
0.8640
0.8511
0.0630
0.0788
1.0
0.8640
0.8640
0.0640
0.0800
The effects of each batch order size parameter θ on production facility indices (λ=0.2, p=0.8, μ=2, α=0.1, and β=0.8).
θ
ρ~
limt→∞Ai(t)
limt→∞Φi(t)
limt→∞Mi(t)/t
0.2
2.1600
1
0.0741
0.0926
0.3
1.4400
1
0.0741
0.0926
0.4
1.0800
1
0.0741
0.0926
0.5
0.8640
0.8356
0.0619
0.0774
0.6
0.7200
0.6729
0.0498
0.0623
0.7
0.6171
0.5632
0.0417
0.0522
The effects of unpredictable events arrival rate α on production facility indices (λ=0.2, p=0.8, θ=0.5, μ=2, and β=0.8).
α
ρ~
limt→∞Ai(t)
limt→∞Φi(t)
limt→∞Mi(t)/t
0.02
0.8128
0.7765
0.0122
0.0153
0.12
0.8768
0.8506
0.0745
0.0931
0.22
0.9408
0.9271
0.1387
0.1734
0.32
1.0048
1
0.2038
0.2548
0.42
1.0688
1
0.2515
0.3144
0.52
1.1328
1
0.2938
0.3672
By means of analysis results derived in Section 4, the effects of batch order arrival rate λ on production facility indices are presented in Table 1, where we set (p,θ,μ,α,β)=(0.8,0.5,2,0.1,0.8). As to be expected, the four performance indices all increase with increasing value of λ. But for λ≥0.25, three facility indices do not vary. This is because the order and production system becomes unstable. Table 2 shows that the effects of batch order entering probability p during optional jobs on production facility indices for the set of parameters (λ,θ,μ,α,β)=(0.2,0.5,2,0.1,0.8). It can be seen from Table 2 that batch order entering probability does not affect the system load and the system is always stable, whereas limt→∞Ai(t), limt→∞Φi(t), and limt→∞Mi(t)/t all increase monotonously as the value of p increases, which coincides with the intuitive expectations. The effects of each batch order size parameter θ on production facility indices are shown in Table 3 with (λ,p,μ,α,β)=(0.2,0.8,2,0.1,0.8). From Table 3, we observe that the influence of θ on four indices is completely opposite to that of λ. Table 4 reports the effects of unpredictable events arrival rate α on production facility indices. Here we assume that (λ,p,θ,μ,β)=(0.2,0.8,0.5,2,0.8). As shown in Table 4, when α increases, all production facility indices increase monotonously. Furthermore, for α≥0.32, the system becomes unstable and the production facility is always busy. The trends shown by Tables 1–4 are as expected.
From the analysis presented in Tables 1–4, it can be concluded that under the stability condition, that is ρ~<1, the performance indices of production facility are affected by batch order arrival, batch order entering probability, batch order size, and unpredictable events arrival. But as ρ~≥1, production facility indices are not affected by batch order arrival and batch order size, and production facility is always busy. In this case, the system is unstable.
6. Conclusions
In this paper, we develop a probabilistic decomposition method to analyze the performance measures of the repairable server in a single-server Mξ/G/1 queue with p-entering discipline during server vacations. Our method is completely different from common methods used in [1–10] and reveals that the structures of server indices in Poisson input single-server bulk arrival vacation queues are two convolution equations. A special case and comparisons with supplementary variable method indicate that our method is effective and applicable for Poisson input bulk arrival vacation queues with a repairable server and their complex variants. Finally, a stochastic order and production system with a multipurpose production facility is numerically presented for illustrative purpose. In the future, the server performance indices of discrete time bulk arrival vacation queues will be our further work using similar probabilistic decomposition method.
Conflict of Interests
The author declares that there is no conflict of interests regarding the publication of this paper.
Acknowledgments
The author would like to thank the referees and editor for their valuable comments and suggestions. This work is supported by the Basic and Frontier Research Foundation of Chongqing of China (cstc2013jcyjA00008) and the Scientific Research Starting Foundation for Doctors of Chongqing University of Technology (2012ZD48).
CaoJ. H.ChengK.Analysis of an M/G/1 queueing system with repairable service stationLamY.ZhangY. L.LiuQ.A geometric process model for M/M/1 queueing system with a repairable service stationJiaJ.-S.LiuS.-F.Optimal control for a kind of repairable queuing system with regular repairman vacationShiD. H.TianN. S.The queueing system GI/M(M/PH)/1 with a repairable serverWangK.-H.KuoM.-Y.Profit analysis of the M/E_{k}/1 machine repair problem with a non-reliable service stationCoxD. R.The analysis of non-Markovian stochastic processes by the inclusion of supplementary variablesWangJ. T.An M/G/1 queue with second optional service and server breakdownsKeJ.-C.HuangK.-B.PearnW. L.The performance measures and randomized optimization for an unreliable server M[x]/G/1 vacation systemLiuZ. M.WuJ. B.YangG.An M/G/1 retrial G-queue with preemptive resume and feedback under N-policy subject to the server breakdowns and repairsCaoJ. H.Reliability analysis of M/G/1 queueing system with repairable service station of reliability series structureFuhrmannS. W.CooperR. B.Stochastic decompositions in the M/G/1 queue with generalized vacationsCaoJ. H.ChengK.