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Mathematical and Computer Modelling of Dynamical Systems
Methods, Tools and Applications in Engineering and Related Sciences
Volume 25, 2019 - Issue 5
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Original Articles

Performance analysis and optimization of a retrial queue with working vacations and starting failures

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Pages 463-481 | Received 09 Apr 2019, Accepted 22 Aug 2019, Published online: 09 Sep 2019

ABSTRACT

This paper presents a steady-state analysis of an M/M/1 retrial queue with working vacations, in which the server is subject to starting failures. The proposed queueing model is described in terms of the quasi-birth-death (QBD) process. We first derive the system stability condition. We then use the matrix-geometric method to compute the stationary probability distribution of the orbit size. Some performance measures for the system are developed. We construct a cost model, and our objective is to determine the optimal service rates during normal and vacation periods that minimize the expected cost per unit time. The canonical particle swarm optimization (CPSO) algorithm is employed to deal with the cost optimization problem. Numerical results are provided to illustrate the effects of system parameters on the performance measures and the optimal service rates. These results depict the system behaviour and show how the CPSO algorithm can be used to find numerical solutions for optimal service rates.

1. Introduction

In retrial queues with a single server, customers who find the server occupied upon arrival join the retrial group (orbit) to retry obtaining service after a random period of time. If the server is free when a customer arrives, then the customer is served immediately. Over the last two decades, intensive research has been conducted on retrial queues due to their wide applicability in telecommunication networks, communication systems, cellular mobile network, telephone switching systems, and computer networks. For a comprehensive survey on retrial queues, we refer the reader to two survey papers by Yang and Templeton [Citation1] and Shekhar et al. [Citation2]; three bibliographies of Artalejo [Citation3Citation5]; and two books by Falin and Templeton [Citation6] and Artalejo and Gomez-Corral [Citation7].

In most of the literature on queueing systems, the server is assumed to be reliable (i.e., never fails). However, in the real world, servers are subject to breakdowns and/or repairs. When a breakdown occurs, service is interrupted until the failed server has been repaired. Retrial queues with server breakdowns have been addressed by many authors, including Sherman and Kharoufeh [Citation8], Falin [Citation9], Choudhury and Ke [Citation10], and Chang et al. [Citation11]. One important feature of retrial queues with server breakdowns is the issue of starting failure. Yang and Li [Citation12] described retrial queues with starting failures as follows: ‘If the server is idle, an arriving customer turns on the server in a negligible time. If the server is started successfully (with a certain probability), the customer gets service immediately. Otherwise, the server is sent to repair immediately, and the customer leaves the service area and repeats the request at a later time.’ They derived analytical results for the queue length distribution of M/G/1 retrial queues with starting failures, where it was assumed that retrial times are exponentially distributed. Kumar et al. [Citation13] subsequently investigated the M/G/1 retrial queue with starting failures and feedback, where it was assumed that retrial times are generally distributed. Wang and Zhao [Citation14] extended the work of Yang and Li [Citation12] to a discrete-time Geo/G/1 retrial queue with second optional service. Atencia et al. [Citation15] used the generating function technique to analyse a discrete-time Geo/G/1 retrial queue with general retrial times and Bernoulli feedback, in which the server is subject to starting failures. Wang and Zhou [Citation16] derived the steady-state probabilities for the M[X]/G/1 retrial queue with starting failures and Bernoulli feedback, where Bernoulli admission control was used for each individual customer. Multi-server retrial systems with starting failures were presented by Yang et al. [Citation17] and Ke et al. [Citation18].

In many real-world systems, the server becomes unavailable for a random amount of time (referred to as vacation time) immediately upon the departure of the last customer from the system. Vacation times can be used to perform tasks such as maintenance work or cleaning operations. The queueing systems with server vacations introduced by Levy and Yechiali [Citation19] are widely used in manufacturing systems, production systems, service systems, inventory systems, and other stochastic systems. The literature on vacation queueing models is extensive. Excellent surveys on this topic can be found in [Citation20Citation23]. During such vacation periods, the server stops working completely; however, in many practical cases, the server continues working during vacation periods. This type of vacation policy (referred to as a working vacation) was introduced by Servi and Finn [Citation24] for the analysis of wavelength-division multiplexing optical access network using multiple wavelengths. Servi and Finn [Citation24] considered an M/M/1 queue with working vacations, wherein vacation times are exponentially distributed. Most of the earlier work on queueing models with working vacations can be found in the survey papers of Tian et al. [Citation25] and Chandrasekaran et al. [Citation26]. The M/M/1 retrial queue with working vacations was first studied by Do [Citation27], who derived closed-form solutions for the steady-state probabilities pertaining to the number of customers in the orbit. Li et al. [Citation28] and Liu and Song [Citation29] extended this work to discrete-time Geo/Geo/1 queues. Tao et al. [Citation30] generalized the model of Do [Citation27] to include vacation interruptions and collisions. Li et al. [Citation31] employed the probability generating function method to obtain the stationary probability distribution of M/M/1 retrial queues with working vacations and vacation interruption. Arivudainambi et al. [Citation32] used the method of supplementary variables to analyse the M/G/1 retrial queue with general retrial times and a single working vacation. Gao et al. [Citation33] used the same method to study the M/G/1 retrial queue with working vacations and vacation interruptions. Li et al. [Citation34] extended the model of Gao et al. [Citation33] to M/G/1 retrial queues with working vacations and vacation interruptions under Bernoulli scheduling, wherein arriving customers may balk (with a certain probability) upon finding that the server is busy. Recently, Do et al. [Citation35] investigated the equilibrium and socially optimal balking strategies of customers in M/M/1 retrial queues with working vacations.

In light of the practical applications of working vacations and service interruptions, this study focuses on retrial queues with working vacations and starting failures. Such a queueing model has potential applications in a health-care scenario. Rapid economic development and improving living standards have raised awareness of health-related matters and the demand for medical services. Some hospitals or clinics provide online consultation services to resolve the problem of long on-site queues. This allows patients to consult with a doctor without having to wait in line. Following this initial consultation, the patients may visit the hospital for further examination if necessary. Such consultation service also helps patients save time and money. We consider an online medical consultation service system, which operates via an APP running on a mobile device. A doctor is responsible for providing medical consultation services. Unfortunately, server disconnections or software bugs lead to inconsistencies in the provision of service (i.e., starting failure in queueing terminology). When no patients are waiting for online consultation service, the doctor is free to leave the system in order to perform other tasks, such as taking care of patients. While the doctor is absent from the system, a chatbot provides consultation services. After a period of time, the doctor returns to the online service to take over from the chatbot. Therefore, the proposed queueing model would be suitable for studying the above scenario.

The remainder of this paper is organized as follows. In Section 2, we present a description of the proposed model and the underlying assumptions. In Section 3, the stationary analysis of the M/M/1 retrial queue with working vacations and starting failures is presented in terms of the quasi-birth-death (QBD) process. We obtain the closed-form expression of the stability condition and use the matrix-geometric method to compute the steady-steady probability distribution. In Section 4, we develop the performance measures for the system. In Section 5, we deal with a cost optimization problem and provide numerical examples to illustrate the effects of parameters on optimal service rates. A special case and numerical comparisons are also presented. Conclusions are drawn in Section 6.

2. The model description and assumptions

In this paper, we consider an M/M/1 retrial queue with working vacations and starting failures, where arrivals follow a Poisson process with rate λ. We assume that new arrivals who find the server unavailable enter an orbit from which connection attempts are repeated until the requested service is completed. The intervals between successive connection attempts (retrials) are exponentially distributed with rate nγ when there are n customers in orbit. To make the analysis tractable, customers in orbit are permitted to conduct retrials up to N(1) retrials. In other words, the retrial rate is min{n,N}γ if the number of customers in orbit is n. The server leaves for a vacation at the instant the system becomes empty. Vacation times follow an exponential distribution with parameter ν. During a vacation period, the server continues working at a lower level, rather than halting service entirely. If the system remains empty when a vacation ends, then the server takes another vacation. Service times during normal busy and vacation periods are exponentially distributed with parameters μb and μv ( < μb), respectively.

In cases where the server is on vacation when an arrival occurs, the arrival triggers the server to switch on with probability δ. When the server is operating normally during busy periods, the probability that service will be commenced for a new or returning customer is θ. If the server is successfully started, then the customer is served immediately. Otherwise, the server is sent for repairs, and the repair time follows an exponential distribution with parameter β. In the event that a server fails, the customer is moved into an orbit form which retrial requests are forwarded. The inter-arrival times, vacation times, service times during normal busy and vacation periods, and repair times are mutually independent. Henceforth, we refer to the above model as the M/M/1/WV retrial queue with starting failures. The general structure of the queueing model is illustrated in .

Figure 1. Basic model for an M/M/1/WV retrial queue with starting failures.

Figure 1. Basic model for an M/M/1/WV retrial queue with starting failures.

3. Stability condition and stationary distribution

Let L(t) be the number of customers in the orbit at time t, and ς(t) be the state of the server at time t, where

ς(t)=0,if the server is down during aworking vacation period at time t,1,if the server is idle during aworking vacation period at time t,2,if the server is busy during aworking vacation period at time t,3,if the server is down during anormal busy period at time t,4,if the server is idle during anormal busy period at time t,5,if the server is busy during anormal busy period at time t.

The M/M/1/WV retrial queue with starting failures can be modelled using a two-dimensional continuous-time Markov process {(ς(t),L(t)),t0} with state space Ω={(1,0),(2,0),(5,0)}{(i,n):0i5, n1}. A Markov process is a QBD process when its one-step transitions from each state are restricted to states in the same level or in the two adjacent levels (see Van Leeuwaarden et al. [Citation36]). Thus, the stochastic process {(ς(t),L(t)),t0} is a QBD process. The state transition diagram is depicted in . Using the lexicographical sequence for the states, the infinitesimal generator Q of the process has the block structure as follows:,

Q=A0B0C1A1BC2A2BCN1AN1BCNANB,

Figure 2. The state transition diagram for an M/M/1/WV retrial queue with starting failures.

Figure 2. The state transition diagram for an M/M/1/WV retrial queue with starting failures.

where

A0=λλδ0μvλ+μv0μb0λ+μb,B0=λδˉ0000000λ00000000λ,
C1=0000γδ000000000γθ000.

Ai, B, and Ci are square matrices of order 6, given by

Ai=AiwvVO3Ainb, i1, B=λ00000λδ0000000λ000000λ00000λθˉ0000000λ,

Ci=00000000iγδ00000000000000000000iγθ000000, i2,

where

Aiwv=λ+β+vβ0iγδˉλ+iγ+vλδ0μvλ+μv+v,
Ainb=λ+ββ0iγθˉλ+iγλθ0μbλ+μb,

O3 is a zero matrix of size 3×3, and V is a 3×3 diagonal matrix with diagonal elements equal v.

3.1. Stability condition

We first study the stability condition of the system. To this end, let us define the invariant probability vector x=x0,x1,x2,x3,x4,x5 that satisfies xB+AN+CN=06 and xe6=1, where 06 is a zero row vector of length 6, and e6 denotes the identity column vector of order 6. Based on Theorem 3.1.1 in Neuts [Citation37], it follows that xCNe6 > xBe6. Then, the necessary and sufficient condition for the system to be stable is

(1) λθˉθβ+λμb+λλ+Nγθ < 1(1)

Remark: If N=1 and θ=1, the stability condition becomes γ > λ2μbλ, which coincides with Do [Citation27].

3.2. Stationary distribution

If the stability condition is fulfiled, let (ς,L) be the stationary limit of the QBD process {(ς(t),L(t))}. We define the steady-state probability vectors as

p0=[p1,0,p2,0,p5,0]; pi=[p0,i,p1,i,p2,i,p3,i,p4,i,p5,i,p6,i], i1,
pi,n=P(ς=i, L=n)=limtP(ς(t)=i, L(t)=n), (i, n)Ω.

We denote the steady-state probability vector using P=p0,p1,p2,..., which satisfies the steady-state equations PQ=0 and the normalization condition Pe=1, where 0 is a zero row vector and e is a column vector with ones. Based on Neuts [Citation37], the steady-state probability vector pN,pN+1,pN+2,... takes the following geometric form:

(2) pi=pNRiN,iN,(2)

where R is the minimal nonnegative solution to the matrix-quadratic equation

(3) B+RAN+R2CN=O6,(3)

and O6 is a zero matrix of size 6×6. The spectral radius of the matrix R is less than one if the stability condition is satisfied. We numerically compute matrix R using the iterative method. Starting with the initial value R0=O6, the following iteration is executed until the sum of the absolute value of all elements of the matrix is smaller than 105, i.e., e6TB+RAN+R2CNe6 < 105.

(4) Ri+1=(B+Ri2CN)AN1,i=0,1,2,...(4)

The steady-state equations PQ=0 can be written as

(5) p0A0+p1C1=03,(5)
(6) p0B0+p1A1+p2C2=06,(6)
(7) pi1B+piAi+pi+1Ci+1=06,2iN1,(7)
(8) pN1B+pNAN+pNRCN=06,(8)
(9) pNRi1NB+RAN+R2CN=06,iN+1,(9)

where 03 represents a row vector of length 3, in which all elements are zero.

Since the determinant of the matrix A0 is λ(λ+μb)(λ+δˉμv)0, the matrix A0 is non-singular and its inverse exists. After some manipulations, Equations (5)–(7) become

(10) p0=p1(C1A01)=p1ψ1,(10)
(11) p1=p2C2(ψ1B0+A1)1=p2ψ2,(11)
(12) pi1=piCi(ψi1B+Ai1)1=piψi,3iN,(12)

where ψ1=(C1A01), ψ2=C2(ψ1B0+A1)1, and ψi=Ci(ψi1B+Ai1)1 for 3iN. Substituting Equations (10)–(12) into Equation (8) gives

(13) pNψNB+AN+RCN=06.(13)

The vector pN is determined by Equation (13) and the normalization condition

(14) p0e3+i=1pie6=pNj=N1ψje3+i=2Nj=Niψje6+IR1e6=1.(14)

Then, the vectors pi (0iN1, iN+1) can be obtained using Equations (2) and (10)–(12).

4. Performance measures

Once the steady-state probability vector has been obtained, we are able to develop the following performance measures for the system.

  • The expected number of customers in the system

(15) Ls=pNj=N1ψj×[0,1,1]T+i=2Nj=Niψj×ie6[1,1,0,1,1,0]T+IR1×Ne6+[0,0,1,0,0,1]T+RIR2e6.(15)
  • The expected number of customers in the orbit

(16) Lo=pNi=2Nj=Nii1ψj+NIR1+RIR2e6.(16)
  • The probability that the server is on vacation

(17) PV=pNj=N1ψj×[1,1,0]T+i=2Nj=Niψj+IR1×[1,1,1,0,0,0]T.(17)
  • The probability that the server undergoes repair

(18) PD=pNi=2Nj=Niψj+IR1×[1,0,0,1,0,0]T.(18)
  • The probability that the server is idle and waits for newly arriving or retrial customers

(19) PI=pNj=N1ψj×[1,0,0]T+i=2Nj=Niψj+IR1×[0,1,0,0,1,0]T.(19)
  • The probability that the server is busy

(20) PB=pNj=N1ψj×[0,1,1]T+i=2Nj=Niψj+IR1×[0,0,1,0,0,1]T.(20)

In the following, we present numerical results illustrating the influence of various system parameters on some performance measures. The numerical results are computed using a PC with an Intel Core i5-7500 CPU and 16 GB RAM running R software (version 3.5.0). We fix N=30 and consider the following eight cases:

Case 1: μv=1.0, μb=2.5, β=1.0, v=0.2, γ=2.0, δ=0.9 and θ=0.8 for various values of λ.

Case 2: λ=1.0, μb=2.5, β=1.0, v=0.2, γ=2.0, δ=0.9 and θ=0.8 for various values of μv.

Case 3: λ=1.0, μv=1.0, β=1.0, v=0.2, γ=2.0, δ=0.9 and θ=0.8 for various values of μb.

Case 4: λ=1.0, μv=1.0, μb=2.5, v=0.2, γ=2.0, δ=0.9 and θ=0.8 for various values of β.

Case 5: λ=1.0, μv=1.0, μb=2.5, β=1.0, γ=2.0, δ=0.9 and θ=0.8 for various values of v.

Case 6: λ=1.0, μv=1.0, μb=2.5, β=1.0, v=0.2, δ=0.9 and θ=0.8 for various values of γ.

Case 7: λ=1.0, μv=1.0, μb=2.5, β=1.0, v=0.2, γ=2.0 and θ=0.8 for various values of δ.

Case 8: λ=1.0, μv=1.0, μb=2.5, β=1.0, v=0.2, γ=2.0 and δ=0.9 for various values of θ.

In each case, the selection of all system parameters fulfils the condition for stability. The behaviours of the performance measures for cases 1–8 are visualized in , respectively. shows that Ls increases with an increase in λ. This may be due to the fact that any increase in the arrival rate would promote an increase in the number of customers who find the server unavailable (busy or failed) and are subsequently moved into the retrial orbit. Conversely, and show that Ls decreases as μv or μb increases. In , we can see that the mean arrival rate (λ) and the mean service rates (μv and μb) have counter effects on probabilities PV, PD, PI, and PB. We can see in that an increase in β leads to (i) Ls and PD decrease, and (ii) PV, PB and PI increase. This can be attributed to the fact that any increase in the repair rate would increase the probability of keeping the server available or operational. In , it is obvious that Ls, PB and PV decrease with an increase in the value of ν. We can also see that PI increases as ν increases. shows that the larger is γ, the smaller are Ls and PI. Furthermore, any increase in γ would lead to increases in PB and PV. Thus, it is reasonable that an increase in γ would lead to an increase in the frequency with which customers make repeated attempts to access service. Moreover, and show that PD is insensitive to change in ν or γ. and clearly show that (i) Ls and PD decrease with an increase in δ or θ, and (ii) PI, PV and PB increase as δ or θ increases. Based on the figures described above, we can conclude that the behaviour of the performance measures is generally in line with our expectations.

Figure 3. Effect of λ on LS, PV, PD, PI, and PB (case 1).

Figure 3. Effect of λ on LS, PV, PD, PI, and PB (case 1).

Figure 4. Effect of μv on LS, PV, PD, PI, and PB (case 2).

Figure 4. Effect of μv on LS, PV, PD, PI, and PB (case 2).

Figure 5. Effect of μb on LS, PV, PD, PI, and PB (case 3).

Figure 5. Effect of μb on LS, PV, PD, PI, and PB (case 3).

Figure 6. Effect of β on LS, PV, PD, PI, and PB (case 4).

Figure 6. Effect of β on LS, PV, PD, PI, and PB (case 4).

Figure 7. Effect of ν on LS, PV, PD, PI, and PB (case 5).

Figure 7. Effect of ν on LS, PV, PD, PI, and PB (case 5).

Figure 8. Effect of γ on LS, PV, PD, PI, and PB (case 6).

Figure 8. Effect of γ on LS, PV, PD, PI, and PB (case 6).

Figure 9. Effect of δ on LS, PV, PD, PI, and PB (case 7).

Figure 9. Effect of δ on LS, PV, PD, PI, and PB (case 7).

Figure 10. Effect of θ on LS, PV, PD, PI, and PB (case 8).

Figure 10. Effect of θ on LS, PV, PD, PI, and PB (case 8).

5. The cost model and optimization

We construct an expected cost function per unit time, in which the service rates μv and μb are decision variables. We define the cost elements as follows:

Ch holding cost per unit time per customer in the system;

Cv cost per unit time when the server is on vacation;

Cb cost per unit time when the server is busy;

C1 cost per customer served under mean service rate μv;

C2 cost per customer served under mean service rate μb.

Based on the above definitions of the cost elements and the corresponding performance measures of the system, the expected cost function per unit time can be derived as follows:

(21) F(μv,μb)=ChLs+CvPV+CbPB+C1μv+C2μb,(21)

where Ls, PV and PB are obtained using Equations (15), (17) and (20), respectively. In Equation (21), the first term refers to the cost incurred by customers in the system, and the last four terms denote the costs incurred by the server. Our purpose is to determine the optimal service rates (μv,μb) by minimizing the expected cost function shown in Equation (21), where F(μv,μb) represents the corresponding minimum value of the expected cost function; i.e. F(μv,μb)=minμv,μb F(μv,μb). The expected cost function is complex and rigorous, making it difficult to derive explicit expressions for the optimal service rates. We, therefore, calculate numerical solutions.

5.1. Canonical particle swarm optimization algorithm

The particle swarm optimization (PSO) algorithm introduced by Kennedy and Eberhart [Citation38] is an efficient stochastic approach to optimizing continuous nonlinear functions. For more information on the PSO algorithm, readers are referred to [Citation39Citation41]. In this study, we utilize the canonical particle swarm optimization (CPSO) algorithm presented by Carlisle and Dozier [Citation42] to obtain numerical results for (μv,μb). The CPSO algorithm has been widely used by several researchers to solve optimization problems in a variety of queueing systems ([Citation43Citation47]). To approximate an optimal solution for (μv,μb), we implement the following procedure based on the CPSO algorithm.

Step 1: Set t=0, the population size M, the upper bound of the position value Xmax, and the lower bound of the position value Xmin.

Step 2: The initial positions and velocities of particles are randomly generated as follows: Xi(t)=(x1,i(t),x2,i(t)) and Vi(t)=(v1,i(t),v2,i(t)), where i=1,2,...,M.

Step 3: Assess the fitness values of each particle using the expected cost function in Equation (21); i.e., F(Xi(t))=F(x1,i(t),x2,i(t)).

Step 4: The initial position of the particle i is set to the initial personal best position of the particle i (pbesti(0)), and the initial global best position of all particles is set to gbest=arg1iN{minF(Xi(0))}.

Step 5: Update the velocity of each particle using the following equation:

            vd,i(t+1)=Υvd,i(t)+c1r1(pbesti(t)xd,i(t))+c2r2(gbest(t)xd,i(t)), Xmin < xd,i(t) < Xmax,0,otherwise,

where d=1,2 and i=1,2,...,M. We generate random values for r1 and r2 in [0, 1]. Note that Υ=2/|2φφ24φ| is the constriction coefficient, and φ is the sum of acceleration constants c1 and c2; i.e. φ=c1+c2. Moreover, c1 and c2 are set to 2.8 and 1.3, respectively.

Step 6: Update the position of each particle using the following equation:

xd,i(t+1)=xd,i(t)+vd,i(t+1),Xmin < xd,i(t)+vd,i(t+1) < Xmax,Xmax,xd,i(t)+vd,i(t+1) > Xmax,Xmin,xd,i(t)+vd,i(t+1) < Xmin.

Step 7: Update the personal best position of particle i (pbesti(t)) and the global best position of all particles gbest.

Step 8: Update the iteration counter t=t+1.

Step 9: Stopping criterion: If max1i  MF(Xi(t))min1j  MF(Xj(t)) is less than tolerance ε, then the algorithm terminates; else return to Step 5.

Step 10: Output (μv,μb)=gbest and F(μv,μb).

5.2. Numerical results

In the following, we present a numerical experiment to check the convexity of F(μv,μb). The graphical representation of F(μv,μb) is plotted in with the following parameter setting: N=30, λ=1.0, γ=2.0, β=1.0, v=0.2, δ=0.9, θ=0.8, Ch=45, Cv=60, Cb=90, C1=30, and C2=15. shows that F(μv,μb) is convex with respect to service rates μb and μv; i.e. there exists a (local) minimum in the surface of the expected cost. We find the minimum expected cost using the CPSO algorithm to approximate the optimal values for μb and μv. We then explore the sensitivity of the approximate optimal service rates (μv,μb) with respect to various system parameters. In implementing the CPSO algorithm, we fix the upper and lower bounds of μb and μv at 0 and 10λ, respectively. The population size is set to 500 (M=500), and the tolerance is set to 0.01 (ε=102). The results are given in , wherein CPU time represents the running time (in seconds) of the algorithm.

Table 1. Optimal service rates (μv,μb) and the corresponding expected cost F(μv,μb) for different values of λ.

Table 2. Optimal service rates (μv,μb) and the corresponding expected cost F(μv,μb) for different values of β.

Table 3. Optimal service rates (μv,μb) and the corresponding expected cost F(μv,μb) for different values of v.

Table 4. Optimal service rates (μv,μb) and the corresponding expected cost F(μv,μb) for different values of γ.

Table 5. Optimal service rates (μv,μb) and the corresponding expected cost F(μv,μb) for different values of δ.

Table 6. Optimal service rates (μv,μb) and the corresponding expected cost F(μv,μb) for different values of θ.

Figure 11. Expected cost F(μv,μb) for various values of μv and μb.

Figure 11. Expected cost F(μv,μb) for various values of μv and μb.

From , we can see that μv and μb increase with an increase in λ. This can be attributed to the fact that an increase in the arrival rate would increase the probability of congestion. An increase in the service rate would decrease the congestion of the system. From , it reveals that μb decreases with an increase in the value of β. shows that μv decreases and μb increases as v increases. It is noted that μv remains at 0 even when v is varied between 1.1 and 1.5. As shown in , μv increases and μb decreases with an increase in γ. In , one can see that an increase in δ causes μv to increase and μb to decrease. We can see in that μv decreases when θ is varied from 0.55 to 0.9. Furthermore, increasing θ leads to a decrease in μb. As shown in , F(μv,μb) increases with an increase in the value of λ and decreases with an increase in any one of the parameters β, v, γ, δ, or θ. The results listed above demonstrate that system managers could optimize system costs by adjusting various system parameters. This observation provides a useful reference for decision-making.

5.3. A special case and numerical comparison

The model of Do [Citation27] is a special case of our model when δ=θ=1 (the server always starts successfully) and N=1 (constant retrial policy). We set τ=δ=θ and choose the system parameters as N=1, λ=1.0, γ=3.0, β=3.0, and v=0.2. The cost elements are identical to those used in Section 5.2. We select different values of τ to compare the numerical results with Do [Citation27]’s model. Given the mean service rates μv=3.5 and μb=6.5, shows that the effects of τ on some performance measures. It reveals that Ls and PD decrease as τ increases. This is because that when τ increases, the server is less prone to breakdowns, which leads to the smaller value of LS and PD. It is also found that PV, PI and PB increase with an increase in τ. shows the optimal service rates (μv,μb) and the corresponding expected cost F(μv,μb) for different values of τ. From , we observe that μv increases and μb decreases as τ increases. Moreover, it is found that F(μv,μb) decreases with increasing values of τ. Therefore, we conclude that the probability τ has an impact on the performance measures, the optimal service rates, and the minimum expected cost per unit time.

Table 7. Optimal service rates (μv,μb) and the corresponding expected cost F(μv,μb) for different values of τ.

Figure 12. Effect of τ on LS, PV, PD, PI, and PB.

Figure 12. Effect of τ on LS, PV, PD, PI, and PB.

6. Conclusions

In this paper, we analysed the M/M/1/WV retrial queue with starting failures. The proposed queueing model was described by a QBD process. We first derived the stability conditions of the model. We then used the matrix-geometric method to obtain the stationary probability distribution and developed a number of performance measures. We formulated a cost optimization problem to determine the optimal service rates (μv,μb) at the minimum expected cost per unit time. The CPSO algorithm was employed to obtain numerical solutions for (μv,μb). We also examined the effects of various system parameters on performance measures and (μv,μb) through numerical experiments. In future works, the arrival process could be extended to the Markovian arrival process. Another direction would be to study the proposed queueing model within scenarios involving multiple servers.

Acknowledgments

The authors thank two anonymous referees for their valuable comments on this manuscript. This work was partially supported by the Ministry of Science and Technology, Taiwan, under Grant No. MOST 107-2218-E-009-058-MY2.

Disclosure statement

No potential conflict of interest was reported by the authors.

Additional information

Funding

This work was partially supported by the Ministry of Science and Technology, Taiwan [MOST 107-2218-E-009-058-MY2].

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