Advances in Operations Research

Advances in Operations Research / 2015 / Article

Research Article | Open Access

Volume 2015 |Article ID 102824 | 12 pages | https://doi.org/10.1155/2015/102824

Queue Length and Server Content Distribution in an Infinite-Buffer Batch-Service Queue with Batch-Size-Dependent Service

Academic Editor: Konstantina Skouri
Received06 Jul 2015
Accepted15 Sep 2015
Published04 Oct 2015

Abstract

We analyze an infinite-buffer batch-size-dependent batch-service queue with Poisson arrival and arbitrarily distributed service time. Using supplementary variable technique, we derive a bivariate probability generating function from which the joint distribution of queue and server content at departure epoch of a batch is extracted and presented in terms of roots of the characteristic equation. We also obtain the joint distribution of queue and server content at arbitrary epoch. Finally, the utility of analytical results is demonstrated by the inclusion of some numerical examples which also includes the investigation of multiple zeros.

1. Introduction

Recently, Banerjee and Gupta [1] analyzed a finite-buffer batch-service queue with batch-size-dependent service and obtained joint distribution of queue and server content (i.e., number in the queue as well as with the server) at departure and arbitrary epochs. However, no such results are available so far in case of an infinite-buffer queue. This paper considers an infinite-buffer single server queue with Poisson arrivals and general service time distribution where customers are served in batches according to general bulk service, rule, and service times of the batches depend on the number of customers within the batch under service process. It is often challenging to obtain the joint distribution of queue and server content of this model due to the enumerable state space and increase in dimensionality that arises in this case. Our main objective in this paper is to develop a tractable yet easily implementable procedure to obtain the joint distribution of the queue and the server content at departure and arbitrary epochs. Banerjee and Gupta [1] used embedded Markov chain technique to analyze the finite-buffer queue wherein they first obtain transition probability matrix (TPM), which appears to be very complex in structure. Further it becomes quite challenging (if not impossible) to extend this TPM for the case of infinite-buffer queue and then to find out the analytic expression of probability generating function (pgf) of queue and server content. In this paper, we use supplementary variable technique (which essentially surpasses the direct use of the TPM) to obtain the bivariate pgf of queue and server content at departure epoch of a batch in a much simpler way and also to establish the relation between arbitrary and departure epoch as a byproduct. Therefore, new contributions in this paper are () construction of bivariate pgf of queue and server content at departure epoch of a batch without using embedded Markov chain technique, () extraction of joint distribution (queue and server content) from the bivariate pgf which has been expressed in terms of roots of so called characteristic equation which arise in this case, () illustration of analytical procedure through several numerical examples, and () investigation of the cases even if the characteristic equation has nonzero repeated roots. More precisely, repeated roots occur for Erlang (), ; service time distribution and number of roots depend on the threshold value “” and the maximum capacity “” and multiplicity of each root depends on “”.

Recent studies on this model have been carried out by Bar-Lev et al. [2], who derived the pgf of only queue content at departure epoch but did not use it due to the complexity involved in the inversion process. However, they obtained queue-size distribution by truncating the TPM into a finite state space and then solving a finite number of system of equations. Later, Chaudhry and Gai [3] have considered this pgf and inverted it using the method of roots in order to derive the distribution of queue content only. It may be noted that both authors did not obtain distribution of queue content at arbitrary epoch. Moreover, from their analysis, one can not get joint distribution of queue and server content.

As a counterpart of continuous-time queues, in discrete-time queues, a series of papers, considered by Claeys et al. [46] deals with such queues. In [4], they considered queue and obtained joint pgf of the queue and the server content and from this they extracted marginal pgfs. However, they stayed away from inverting the joint pgf to obtain complete joint distribution of queue and server content rather restricted on finding tail distribution and performance measures only. Further, in [5], they analyze the same queueing model under discrete-batch Markovian arrival process (D-BMAP) and derived joint vector generating function of the queue content, the server content, and the remaining service time of the batch under service and then extracted marginal pgfs for several admissible quantities such as queue content when server is inactive, server content is at the end of service, and so forth. They also elaborated upon the influence of correlation of the arrival process on the mean system content. Furthermore, in [6], they approximated tail probabilities of the customer delay in queue. It has been emphasized that neglecting of batch-size-dependent service can lead to a devastating inaccuracy of the approximation of the tail probabilities.

The rest of the paper is organized as follows: the next section describes the model in detail and governing equations. Section 3 contains the derivation of bivariate pgf and extraction of joint distribution from that pgf at departure epoch of a batch. The joint distribution at arbitrary epoch is obtained in Section 4 while Section 5 shows the applicability of our analytical results through some specific service time distributions. The paper ends with conclusion.

2. Model Description and Governing Equations

Although the model description and governing equations have been well discussed by Banerjee and Gupta [1] for finite-buffer queue, however, for the sake of completeness it is again discussed briefly in case of infinite-buffer.(i)Arrival Process. Customers arrive at the system according to Poisson process with rate .(ii)Batch-Service Discipline. The single server serves the customers in batches according to general bulk service () rule.(iii)Service Process. The service time () of a batch of size () follows general distribution with probability density function (p.d.f.) , distribution function , the Laplace-Stieltjes transform (L.-S.T.) , and the mean service time , , where is the derivative of evaluated at .(iv)Utilization Factor. The traffic intensity of the system which ensures the stability of the system.Let us define the state of the system at time as (i) ≡ number of customers in the queue waiting for service,(ii) ≡ number of customers with the server,(iii) ≡ remaining service time of the batch in service.Further, we defineIn steady-state, let us defineRelating the states of the system at two consecutive time epochs and and using supplementary variable technique, we obtain, in steady-state, the following differential equations:Further, let us defineMultiplying (5)–(8) by and integrating with respect to over 0 to , we obtainAs our major concern is to perceive the joint distribution of queue content as well as server content at departure and arbitrary epoch, we define the following probabilities at departure epoch:Now we propose the following lemmas which will be used later.

Lemma 1. The probabilities and are connected by the relation

Proof. As is proportional to , using we obtain the desired result.

Lemma 2. The value of is given bywhere .

Proof. Using (3) in (4), we getUsing (19) in (10), we getSumming (20) and (11) to (13), we obtainTaking limit as in the above expression and using L’Hôspital’s rule, the normalizing condition , and after a little bit of manipulation, we obtain the desired result.

3. Joint Distribution of Queue Content and Number with the Departing Batch

In order to obtain , we further define the following pgfs:Multiplying (10)–(13) by appropriate powers of and , summing over from 0 to and from to and using (22), we getNow substituting in (25) and using (17), (16), (15), and (23), we obtainwhere is the pgf of andSubstituting in (26), using (24) and after a little bit of manipulation, we obtainFinally, using (28) in (26) and after some algebraic simplification, we get

Remark 3. To the best of the authors’ knowledge, no such bivariate pgf (expressed in (29)) of queue content as well as number with the departing batch is available so far in the literature.

Remark 4. The pgf expressed in (28) for the queue content at departure epoch exactly matches with the pgf given in Bar-Lev et al. [2, page 230] which was obtained using embedded Markov chain technique.

One can observe from (29) that is a bivariate pgf and has been expressed in a compact form except for the unknowns . One can further note that these unknowns are the same as those unknowns appearing in the numerator of (28). Now our first task is to get these unknowns from (28) before any further analysis is carried out using (29). Now in order to determine them, we make use of Rouché’s theorem, by which it can be shown that the denominator of (28), , has zeroes (say, ) in the closed complex unit disk . Due to the analytic property of the pgf in the closed complex unit disk, these zeroes are necessarily also zeroes of the numerator of (28), which leads to linear equations asAs we need one more equation in order to get linear equations, we obtain it using normalizing condition . After applying L’Hôspital’s rule, it leads toNow the unknowns can be determined by solving (30) and (31).

3.1. Extraction of Joint Probabilities from the Bivariate pgf

Having found the unknowns , is now completely known to us. Our main objective is to extract the probabilities , from . In order to get these, we need to invert the bivariate pgf . For this purpose, we first accumulate the coefficient of , , from both the sides of (29). These are given asNow collecting the coefficient of from both the sides of (32) and (33), we obtainAs , are already known, we turn our focus on determination of , from (34). In order to get these probabilities, we invert the right hand side of (34) which is a completely known function in for a specific service time distribution.

In order to simplify the calculation, let us assume that the L.-S.T of service time distribution , , is a rational function and is given by , where and are polynomials of degrees and , respectively, with . Then, substituting , in the right-hand side of (34) and after some simplification it can be proved that degree of the numerator of (34) is always less than the degree of the denominator of (34).

Let us denote numerator of (34) as (after dividing the numerator of (34) by the highest power coefficient of the denominator of (34)) and the denominator as . Let us also assume that has degree . To extract the probabilities , we need to know about the zeroes of . Let us call these zeroes . Now applying the partial fraction technique, can be uniquely written asfor some constants ’s, which can be determined using residue theorem asNow collecting the coefficient of from both the sides of (36), we obtainThis completes the evaluation of joint distributions of number of customers in the queue and number with the departing batch at departure epoch of a batch.

Remark 5. It may be remarked here that if some of the zeroes of the characteristic equation are repeated, then the above procedure has to be slightly modified to extract the joint distribution. We have included one such example in the numerical section.

Remark 6. One can also obtain the tail distribution from (34) using single root of . This root is the smallest with absolute value greater than one, real and strictly positive. Otherwise, if the denominator has two complex conjugate zeros or one negative real zero with smallest modulus, this can lead to negative probabilities for sufficiently large values of ; see Desmet et al. [7]. Thus, we can find the following approximation of the tail distribution for sufficiently large as and is the real positive zero of with the smallest modulus greater than one.

Remark 7. For some specific service time distributions, the probabilities , can be easily computed by inverting the pgf .

4. Joint Distribution of Queue and Server Content at Arbitrary Epoch

Utilizing the completely known distribution of queue and server content at departure epoch of a batch, we develop the following result in order to acquire the distribution of queue and server content at arbitrary epoch. The procedure is similar to the one given in [1, page 62]. However, for the sake of completeness, results are given here for infinite-buffer queue.

Theorem 8. The probabilities and are related bywhere and .

Once the joint distribution of queue and server content at arbitrary epoch is known, we can obtain other significant distributions such as distribution of queue content, , and distribution of the server content in undergoing service, (, and). Moreover, the distribution of the system content (including number of customers with the server), , which is more relevant, is given by As all the state probabilities are known, the utmost performance measures of the present model can be easily evaluated and are presented as follows: (i)Average number of customers in the queue .(ii)Average number of customers in the system .(iii)Average number of customers with the server .(iv)Average waiting time of a customer in the queue as well as in the system .(v)The probability that the server is idle .The above performance measures play a significant role in evaluating the real system.

5. Numerical Illustration

Based on the theoretical analysis in Sections 3 and 4, we illustrate numerical results for assorted service time distributions, namely, exponential (), Erlang (), and deterministic (). Extensive computation work has been executed using Maple 13 http://www.maplesoft.com/products/maple/ on PC running on Windows 7 with Intel Core i5-3470 CPU Processor @ 3.20 GHz with 4.00 GB of RAM, for both the high and low values of the model parameters. Although a vast number of tables can be generated, only a few of them that contain significant results are appended here. Parameter values are displayed at the title of the each table while the bottoms of the tables contain some performance measures.

First we present the joint distribution and , , for exponential () service time distribution in Tables 1-2. The objective of this example is to match our results with the existing results available in the literature.



00.0032640.0006340.0006930.0007510.0008080.0008640.0009180.0009700.0010210.0010700.0011180.012112
10.0031270.0006060.0006590.0007120.0007630.0008120.0008600.0009060.0009500.0009920.0021460.012531
20.0029970.0005780.0006270.0006740.0007200.0007630.0008050.0008450.0008830.0009190.0030900.012903
30.0028710.0005520.0005960.0006390.0006790.0007180.0007540.0007890.0008210.0008510.0039560.013228
40.0027510.0005270.0005670.0006050.0006410.0006750.0007070.0007360.0007640.0007890.0047490.013511
50.0026360.0005030.0005390.0005730.0006050.0006350.0006620.0006870.0007100.0007310.0054720.013754
100.0021290.0003980.0004190.0004370.0004530.0004670.0004780.0004870.0004940.0004990.0082050.014465
500.0003850.0000620.0000560.0000500.0000450.0000400.0000350.0000310.0000270.0000240.0081170.008872
1000.0000450.0000060.0000040.0000030.0000020.0000020.0000010.0000000.0000000.0000000.0026150.002678
2000.0000000.0000000.0000000.0000000.0000000.0000000.0000000.0000000.0000000.0000000.0001700.000170
3000.0000000.0000000.0000000.0000000.0000000.0000000.0000000.0000000.0000000.0000000.0000100.000010
3700.0000000.0000000.0000000.0000000.0000000.0000000.0000000.0000000.0000000.0000000.0000010.000001
380  0.0000000.0000000.0000000.0000000.0000000.0000000.0000000.0000000.0000000.0000000.0000000.000000

0.0780400.0139600.0141320.0142720.0143830.0144650.0145220.0145560.0145670.0145580.7925391.000000



00.0008920.0055070.0009810.0009890.0009960.0010000.0010020.0010020.0010010.0009980.0009930.0009880.016350
10.0018150.0052770.0009370.0009410.0009430.0009430.0009420.0009390.0009340.0009280.0009200.0018970.017417
20.0027650.0050560.0008940.0008950.0008930.0008910.0008860.0008790.0008720.0008620.0008530.0027310.018480
30.0037400.0048450.0008530.0008510.0008460.0008400.0008330.0008240.0008130.0008020.0007900.0034970.019537
40.0047350.0046420.0008140.0008090.0008020.0007930.0007830.0007720.0007590.0007460.0007320.0041970.020587
50.0044480.0007780.0007700.0007600.0007490.0007360.0007230.0007090.0006940.0006780.0048370.015881
100.0035930.0006160.0005980.0005800.0005610.0005410.0005220.0005010.0004820.0004630.0072520.015710
500.0006500.0000960.0000800.0000670.0000550.0000460.0000380.0000320.0000260.0000210.0071750.008288
1000.0000770.0000090.0000060.0000040.0000030.0000020.0000010.0000010.0000000.0000000.0023110.002417
2000.0000010.0000000.0000000.0000000.0000000.0000000.0000000.0000000.0000000.0000000.0001510.000152
3000.0000000.0000000.0000000.0000000.0000000.0000000.0000000.0000000.0000000.0000000.0000090.000009
3700.0000000.0000000.0000000.0000000.0000000.0000000.0000000.0000000.0000000.0000000.0000010.000001
3800.0000000.0000000.0000000.0000000.0000000.0000000.0000000.0000000.0000000.0000000.0000000.000000

Total 0.013947 0.131681 0.021593 0.020178 0.018923 0.017798 0.016781 0.015856 0.015010 0.014231 0.013511 0.700489 1.000000

, , and
, , and

The numerical results given in Table 2 using our methodology for exponential () service time distribution exactly match with the existing results of Table 3 given in Maity and Gupta [8]. The results presented in column 2 and row 1 of Table 2 match exactly with the last two rows of Table  3 of [8] which was obtained as a special case from queue. The methodology used in [8] is the matrix geometric method while we use probability generating function approach. It may be remarked here that, in [8], there is a misprint in the value of the arrival rate . It should be and other parameters (which are shown in Table 2) in our example are taken the same as in [8].



00.0002580.0000990.0001530.0002190.0002920.0003700.0004480.0005240.0005940.002957
10.0008420.0003150.0004730.0006550.0008500.0010480.0012370.0014100.0021090.008939
20.0017190.0006240.0009100.0012250.0015460.0018540.0021330.0023690.0045020.016882
30.0028060.0009890.0014010.0018320.0022490.0026260.0029420.0031850.0074980.025528
40.0040090.0013710.0018860.0023970.0028620.0032530.0035510.0037480.0107380.033815
50.0052370.0017370.0023210.0028670.0033310.0036850.0039180.0040310.0138870.041014
60.0064120.0020640.0026780.0032160.0036340.0039130.0040530.0040650.0166840.046719
70.0074770.0023350.0029430.0034340.0037750.0039570.0039930.0039040.0189620.050780
80.0083930.0025440.0031130.0035310.0037750.0038530.0037870.0036090.0206430.053248
90.0091350.0026870.0031930.0035200.0036610.0036370.0034820.0032350.0217170.054267
100.0096950.0027670.0031930.0034210.0034610.0033470.0031220.0028270.0222200.054053
200.0078890.0016650.0014340.0011560.0008870.0006560.0004700.0003300.0123760.026862
300.0031940.0004990.0003200.0001940.0001130.0000640.0000350.0000190.0038080.008246
400.0009490.0001100.0000520.0000240.0000100.0000040.0000020.0000000.0009610.002112
600.0000530.0000030.0000000.0000000.0000000.0000000.0000000.0000000.0000460.000102
800.0000020.0000000.0000000.0000000.0000000.0000000.0000000.0000000.0000020.000004
850.0000000.0000000.0000000.0000000.0000000.0000000.0000000.0000000.0000000.000000

0.2266520.0532490.0542670.0540530.0528440.0508710.0483440.0454460.4142721.000000

Now we focus on other service time distributions. We have shown the occurrence of multiple roots in case of service time distribution with each phase mean so that total mean is , . The purpose of this example is to demonstrate the occurrence of multiple roots in queueing models which was often a major concern of the researchers. In this context, we point out that the multiple roots occur only for service time distribution. The occurrence of multiple roots is caused by the terms :(i)The number of multiple roots depends on the values of “” and “.” The exact number of distinct multiple roots is .(ii)The multiplicity of each root depends on the parameter (), of Erlang distribution.For distribution with parameters , , , , , and , we have encountered 8 multiple roots: 1.225000, 1.262500, 1.300000, 1.337500, 1.375000, 1.412500, 1.450000, and 1.487500 each of multiplicity 4. The joint distribution of and , is displayed in Tables 3-4.



00.0002530.0193300.0045380.0046200.0045960.0044870.0043110.0040890.0038350.0035630.053622
10.0010160.0192580.0045110.0045800.0045400.0044140.0042220.0039830.0037150.0067230.056962
20.0024580.0191110.0044580.0045020.0044360.0042820.0040640.0038020.0035130.0094040.060030
30.0046370.0188720.0043730.0043820.0042790.0040900.0038400.0035500.0032410.0115600.062824
40.0075250.0185290.0042560.0042210.0040750.0038460.0035620.0032470.0029210.0131820.065364
50.0110270.0180820.0041080.0040230.0038300.0035610.0032470.0029130.0025760.0142900.067657
60.0150160.0175350.0039320.0037950.0035550.0032510.0029130.0025670.0022290.0149300.069723
70.0168960.0037320.0035430.0032620.0029290.0025750.0022260.0018960.0151620.052221
80.0161800.0035150.0032770.0029610.0026060.0022460.0019020.0015880.0150540.049329
90.0154000.0032860.0030050.0026600.0022940.0019360.0016050.0013120.0146740.046172
100.0145720.0030490.0027320.0023680.0019980.0016500.0013380.0010700.0140880.042865
200.0064450.0010640.0007480.0005080.0003360.0002180.0001390.0000880.0058240.015370
300.0020520.0002580.0001380.0000720.0000360.0000180.0000090.0000040.0016420.004229
400.0005370.0000510.0000200.0000080.0000030.0000010.0000000.0000000.0003970.001017
600.0000260.0000010.0000000.0000000.0000000.0000000.0000000.0000000.0000180.000045
750.0000020.0000000.0000000.0000000.0000000.0000000.0000000.0000000.0000010.000003
850.0000000.0000000.0000000.0000000.0000000.0000000.0000000.0000000.0000000.000000

Total 0.041932 0.344036 0.069281 0.061779 0.054699 0.048127 0.042119 0.036691 0.031838 0.269497 1.000000

, , and
, , and

In Tables 5-6, similar results are provided for deterministic () service time distribution. As the L.-S.T. of deterministic () distribution is a transcendental function, we use Padé approximation to approximate its L.-S.T as a rational function of the form . For more details, see Singh et al. [9], where they have discussed choice for parameters for Padé approximation.



00.0003490.0003420.0007030.0010600.0012700.0012700.0010920.006084
10.0025150.0020540.0036130.0047690.0050820.0045710.0042020.026806
20.0090560.0061620.0092910.0107290.0101630.0082280.0082410.061869
30.0217340.0123250.0159280.0160940.0135510.0098740.0110170.100523
40.0391200.0184870.0204790.0181060.0135510.0088870.0113300.129959
50.0563330.0221840.0210640.0162950.0108410.0063980.0095920.142707
60.0676000.0221840.0180550.0122210.0072270.0038390.0069870.138113
70.0695320.0190150.0132650.0078570.0041300.0019740.0045160.120289
80.0625780.0142610.0085270.0044190.0020650.0008880.0026500.095388
90.0500630.0095070.0048730.0022100.0009180.0003550.0014360.069362
100.0360450.0057040.0025060.0009940.0003670.0001280.0007280.046472
120.0141560.0015560.0005020.0001520.0000440.0000130.0001580.016581
140.0040320.0003080.0000730.0000170.0000040.0000000.0000290.004463
160.0008710.0000460.0000080.0000010.0000000.0000000.0000040.000930
180.0001470.0000050.0000000.0000000.0000000.0000000.0000000.000152
200.0000200.0000000.0000000.0000000.0000000.0000000.0000000.000020
230.0000000.0000000.0000000.0000000.0000000.0000000.0000000.000000

0.4679580.1381140.1202890.0953900.0693620.0464730.0624141.000000



00.0009290.0714000.0210360.0182600.0144030.0103970.0069020.0042310.147558
10.0050220.0710160.0207230.0177080.0136750.0096210.0062040.0061220.150090
20.0144700.0696330.0197820.0162890.0120370.0080690.0049480.0062220.151450
30.0298190.0663140.0179000.0138570.0095800.0060000.0034400.0052210.152130
40.0496630.0603410.0150770.0107300.0068150.0039310.0020830.0038120.152452
50.0517390.0116900.0075140.0043270.0022760.0011060.0024890.081141
60.0414170.0083030.0047570.0024610.0011720.0005200.0014820.060112
70.0308000.0053990.0027310.0012610.0005410.0002180.0008160.041766
80.0212450.0032210.0014290.0005860.0002260.0000830.0004210.027211
90.0136010.0017700.0006850.0002490.0000860.0000280.0002050.016624
100.0080970.0008990.0003020.0000970.0000300.0000090.0000940.009528
120.0023330.0001860.0000470.0000120.0000030.0000000.0000180.002599
140.0005200.0000290.0000050.0000010.0000000.0000000.0000030.000558
160.0000920.0000040.0000000.0000000.0000000.0000000.0000000.000096
180.0000130.0000000.0000000.0000000.0000000.0000000.0000000.000013
200.0000010.0000000.0000000.0000000.0000000.0000000.0000000.000001
230.0000000.0000000.0000000.0000000.0000000.0000000.0000000.000000

Total
0.099903
0.514462
0.126533
0.094459
0.065544
0.042364