In this chapter we consider multirate loss models of batched Poisson arriving calls with fixed bandwidth requirements and elastic bandwidth allocation during service. As we have reached the last chapter of the book, the reader should be able to understand the title of this chapter. As a reminder, in the batched Poisson process (in which now a batch consists of two types of calls, elastic or adaptive), simultaneous call‐arrivals (batches) occur at time‐points following a negative exponential distribution. Elastic calls can reduce their bandwidth and simultaneously increase their service time. Adaptive calls can tolerate bandwidth compression without altering their service time.
In the elastic Erlang multirate loss model with batched Poisson arrivals (BP‐E‐EMLM), we consider a link of capacity b.u. that accommodates elastic calls of different service‐classes. Calls of each service‐class have the following attributes: (i) they arrive in the link according to a batched Poisson process with rate and batch size distribution , where denotes the probability that there are calls in an arriving batch of service‐class , (ii) they follow the partial batch blocking discipline (see Chapter 10), and (iii) they request b.u. (peak‐bandwidth requirement). To introduce bandwidth compression in the model, the occupied link bandwidth can virtually exceed up to a limit of b.u. Then the call admission is identical to the one presented in the case of the E‐EMLM (see Section 3.1.1).
Similarly, in terms of the system state‐space , the CAC is expressed as in the E‐EMLM (see Section 3.1.1). Hence, the TC probabilities of service‐class are determined by the state space :
where , is the number of in‐service calls of service‐class in the steady state, , is the steady state probability, and .
The compression/expansion of bandwidth results in a non PFS for the values of , a fact that makes (11.1) inefficient. In order to analyze the service system and provide an approximate but recursive formula for the calculation of the link occupancy distribution, we assume that local flow balance (as described in Chapter 10) does exist across certain levels that separate two adjacent states of . To this end, we present the following notations [1]:
The first step in the analysis is to define the levels across which local flow balance will hold. For the state , with , the level separates from . Then, the “upward” (due to a new service‐class batch arrival) probability flow across level is given by [ 1]:
where , with , and is the corresponding steady state probability.
Equation (11.2) can be also written as follows:
where is the complementary batch size distribution.
The “downward” (due to a service‐class call departure) probability flow across level is given by [ 1]:
where , defined according to (3.2), is the common state dependent factor used to compress/expand the service rate of calls, when their bandwidth is compressed/expanded, since the target is to keep constant the product service time by bandwidth per call.
Due to the compression/expansion mechanism of calls of service‐class the local flow balance across level is destroyed, i.e., or
Similar to the E‐EMLM, are replaced by the state‐dependent compression factors per service‐class and which are defined according to (3.8) and (3.9), respectively.
Having defined and , we make the assumption (approximation) that the following equation holds: or
Before we proceed with the derivation of a recursive formula for the determination of , note that the GB equation for state is still given by (10.10). In (10.10), the “upward” probability flows are given by (11.3) and the “downward” probability flows are given by (11.4) (if we refer to ) or by the RHS side of (11.6) (if we refer to ).
Consider now two different sets of macro‐states: (i) and (ii) . For the first set, no bandwidth compression takes place (i.e., for all and can be determined by (10.16) [2]). For the second set, ( 11.6) based on (3.8) is written as:
where is the offered traffic‐load of service‐class calls (in erl).
Multiplying both sides of (11.7) by and summing over , we have:
Due to (3.9), (11.8) is written as:
Let be the state space where exactly b.u. are occupied. Then, summing both sides of (11.9) over and since , we have:
Interchanging the order of summations in (11.10), we have:
since .
The combination of (10.16) with (11.11) gives the approximate recursive formula of , when [ 1]:
where is the largest integer less than or equal to and is the complementary batch size distribution given by .
If calls of service k arrive in batches of size where is given by the geometric distribution with parameter (for all k) then (11.12) takes the form:
If for and for , for all service‐classes, then we have a Poisson process and the E‐EMLM results (i.e., the recursion of (3.21)).
The following performance measures can be determined based on ( 11.12):
where denotes the probability that there are calls in an arriving batch of service‐class and is the maximum integer not exceeding .
If the batch size is geometrically distributed then (11.15) takes the form:
The proof of (11.16) is similar to the proof of (10) in [3] (which gives the CC probability in the BP‐EMLM where the batch size is geometrically distributed) and therefore is omitted.
Consider again Example 11.1 ().
The normalization constant is: .
The state probabilities (link occupancy distribution) are:
Compared with the values of obtained via in Example 11.1, we see that there exists a slight difference, an indication that local flow balance does not exist.
(compare with 0.262295 in the BP‐EMLM) |
(compare with 0.59016 in the BP‐EMLM) |
CC probabilities:
(compare with 0.3377 in the BP‐EMLM) |
(compare with 0.79508 in the BP‐EMLM) |
Utilization:
b.u. (compare with 1.6475 in the BP‐EMLM) |
In the elastic Erlang multirate loss model with batched Poisson arrivals under the BR policy (BP‐E‐EMLM/BR) a new service‐class call is accepted in the link if, after its acceptance, the link bandwidth , where is the BR parameter of service‐class .
In terms of the system state‐space and due to the partial batch blocking discipline, the CAC is identical to that of the E‐EMLM/BR (see Section 3.2.1). As far as the TC probabilities of service‐class are concerned, they are determined by ( 11.1), where .
The compression factor and the state‐dependent compression factor per service‐class are defined according to (3.2) and (3.8), respectively.
Consider again Example 11.1 () and assume that and , so that . Calculate the values of and the corresponding values of based on the GB equation of (10.10) while assuming:
Then determine the TC probabilities of both service‐classes via ( 11.1). Note that in (10.10), the “upward” probability flows are given by ( 11.3), while the “downward” probability flows are given by ( 11.4) (if we refer to ) or by the RHS of ( 11.6) (if we refer to ).
The state space of this system consists of 11 states of the form . The values of and are exactly the same as those of Table 3.1 (ignore the last row). Similarly, the values of and are exactly the same as those of Table 3.2.
The solution of this linear system is:
Based on the values of , we have:
Based on ( 11.1) and the state space , the TC probabilities are the following:
(compare with 0.3234 in the E‐EMLM/BR) |
The solution of this linear system is:
Based on the values of , we have:
The corresponding TC probabilities are:
(compare with the exact 0.3999) |
In the BP‐E‐EMLM/BR, the unnormalized values of the link occupancy distribution, , can be calculated in an approximate way according to the Roberts method (see Section 1.3.2.2).
Based on Roberts method, ( 11.12) takes the form [ 1]:
where , is the largest integer less than or equal to , is the complementary batch size distribution given by , and is determined via (3.34b).
If calls of service arrive in batches of size where is given by the geometric distribution with parameter (for all ) then (11.18) takes the form:
The following performance measures can be determined based on ( 11.18):
If the batch size is geometrically distributed then (11.21) takes the form:
Consider again Example 11.3 ().
The normalization constant is: .
The state probabilities (link occupancy distribution) are:
(compare with 0.3171 in the E‐EMLM/BR) |
CC probabilities:
(compare with in the E‐EMLM/BR) |
Utilization:
b.u. (compare with 2.049 in the E‐EMLM/BR) |
Consider a link of capacity b.u. that accommodates three service‐classes of elastic calls which require b.u., b.u., and b.u., respectively. All calls arrive in the system according to a batched Poisson process and the batch size follows the geometric distribution with parameters , and , respectively. The service time is exponentially distributed with mean value . The initial values of the offered traffic‐load are erl, erl, and erl. In the ‐axis of all figures, we assume that remain constant, while increases in steps of 0.5 erl. The last value of erl. We consider the following set of BR parameters and . This set achieves TC probabilities equalization among calls of all service‐classes. We also consider three different values of : (a) b.u., where no bandwidth compression takes place (in that case we have the BP‐EMLM/BR), (b) b.u., where bandwidth compression takes place and , and (c) b.u., where bandwidth compression takes place and .
In Figure 11.1 we present the equalized TC probabilities () for all values of . In Figures 11.2–11.4 we present the CC probabilities for the three service‐classes, respectively. All figures show that (i) the accuracy of the BP‐E‐EMLM/BR is absolutely satisfactory compared to simulation (mean values of seven runs with small reliability ranges, not shown in the figures) and (ii) the increase of above results in a decrease of both TC and CC probabilities due to the existence of the compression mechanism.
In the elastic adaptive Erlang multirate loss model with batched Poisson arrivals (BP‐EA‐EMLM) we consider a link of capacity b.u. that accommodates service‐classes which are distinguished into elastic service‐classes and adaptive service‐classes: . The call arrival process remains batched Poisson.
The bandwidth compression/expansion mechanism and the CAC of the BP‐EA‐EMLM are identical to those presented in the case of the E‐EMLM (Section 3.1.1). The only difference is in (3.3), which is applied only on elastic calls (adaptive calls tolerate bandwidth compression without altering their service time). As far as the TC probabilities of service‐class calls are concerned they can be determined via ( 11.1).
Due to the compression/expansion mechanism of calls of service‐class the local flow balance across the level is destroyed, i.e., (11.5) holds for elastic calls while the corresponding formula for adaptive calls is 5,6:
Similar to the BP‐E‐EMLM, are replaced by the state‐dependent compression factors per service‐class , and , which are defined according to (3.8) and (3.47), respectively.
Having defined and , we make the assumption (approximation) that the following equations hold: , or
where the only difference between (11.24) and (11.25) is in .
Before we proceed with the derivation of a recursive formula for the determination of , note that the GB equation for state is given by (10.10). In (10.10), the “upward” probability flows are given by ( 11.3) and the “downward” probability flows are given by (i) ( 11.5) and (11.23) for elastic and adaptive calls, respectively (if we refer to ), or (ii) the RHS of ( 11.24), ( 11.25) (if we refer to ).
Consider again Example 11.1 () and assume that calls of service‐class 2 are adaptive. Calculate the values of and the corresponding values of based on the GB equation of (10.10) and assuming:
Then determine the TC probabilities of both service‐classes via ( 11.1).
The state space of this system consists of 12 states of the form . The values of and are exactly the same as those of Table 3.1 (Example 3.1). Similarly, the values of and are exactly the same as those of Table 3.5 (Example 3.14).
The solution of this linear system is:
Based on the values of , we have:
Based on ( 11.1), the TC probabilities are:
(compare with 0.2279 in the BP‐E‐EMLM) |
(compare with 0.4404 in the BP‐E‐EMLM) |
The solution of this linear system is:
Based on the values of , we have:
Based on ( 11.1), the TC probabilities are:
(compare with the exact 0.1754) |
(compare with the exact 0.3677) |
Similar to the BP‐E‐EMLM, we consider two different sets of macro‐states: (i) and (ii) . For the first set, no bandwidth compression takes place and can be determined by (10.16) [ 2]. For the second set, we substitute (3.8) in ( 11.24) and ( 11.25) to have:
where is the offered traffic‐load of service‐class calls (in erl).
Multiplying both sides of (11.26a) by and summing over , we have:
Similarly, multiplying both sides of (11.26b) by and , and summing over , we have:
By adding (11.27) and (11.28), we have:
Based on (3.47), (11.29) is written as:
Summing both sides of (11.30) over and based on the fact that , we have:
By interchanging the order of summations in (11.31), we obtain:
or
because .
The combination of (10.16) with (11.33) gives the approximate recursive formula of , when [ 5, 6]:
where , is the largest integer less than or equal to and is the complementary batch size distribution given by .
If calls of service arrive in batches of size where is given by the geometric distribution with parameter (for all ) then (11.34) takes the form:
If for and for , for all service‐classes, then we have a Poisson process and the EA‐EMLM results (i.e., the recursion of (3.57)).
The following performance measures can be determined based on ( 11.34):
Consider again Example 11.6 () where calls of service‐class 2 are adaptive.
The normalization constant is: .
The state probabilities (link occupancy distribution) are:
Compared with the values of obtained via in Example 11.6, we see that there exists a slight difference, an indication that local flow balance does not exist.
(compare with 0.221785 in the BP‐E‐EMLM) |
(compare with 0.44391 in the BP‐E‐EMLM) |
CC probabilities:
(compare with 0.27372 in the BP‐E‐EMLM) |
(compare with 0.66498 in the BP‐E‐EMLM). |
Utilization:
b.u. (compare with 2.25 in the BP‐E‐EMLM) |
In the elastic adaptive Erlang multirate loss model with batched Poisson arrivals under the BR policy (BP‐EA‐EMLM/BR) a new service‐class call is accepted in the link if, after its acceptance, the link bandwidth , where is the BR parameter of service‐class .
In terms of the system state‐space and due to the partial batch blocking discipline, the CAC is identical to that of the E‐EMLM/BR (see Section 3.2.1). The only difference is in (3.3), which is applied only on elastic calls. As far as the TC probabilities of service‐class are concerned, they are given by ( 11.1), where .
The compression factor and the state‐dependent compression factor per service‐class , are defined according to (3.2) and (3.8), respectively, while the values of are given by (3.47).
Consider again Example 11.6 () and assume that and , so that . Calculate the values of and the corresponding values of based on the GB equation of (10.10) and assuming:
Note that in (10.10), the “upward” probability flows are given by ( 11.3) and the “downward” probability flows are given by (i) ( 11.4) (if we refer to and elastic calls) or by the RHS of ( 11.23) (if we refer to and adaptive calls) and (ii) by the RHS of ( 11.24) and ( 11.25) (if we refer to ).
The state space of this system consists of 11 states of the form . The values of and are exactly the same as those of Table 3.1 (ignore the last row). Similarly, the values of and are exactly the same as those of Table 3.5.
The solution of this linear system is:
Based on the values of , we have:
Based on ( 11.1) and the state space , the TC probabilities are:
(compare with 0.2674 in the EA‐EMLM/BR) |
The solution of this linear system is:
Based on the values of , we have:
The corresponding TC probabilities are:
(compare with the exact 0.3415) |
In the BP‐EA‐EMLM/BR, the unnormalized values of the link occupancy distribution, , can be calculated in an approximate way according to the Roberts method (see Section 1.3.2.2).
Based on the Roberts method, ( 11.34) takes the form [ 5]:
where = , is the largest integer less than or equal to , is the complementary batch size distribution given by , and is determined via (3.34b).
If calls of service arrive in batches of size where is given by the geometric distribution with parameter (for all ), then (11.38) becomes:
The following performance measures can be determined based on ( 11.38):
Consider again Example 11.7 ()
The normalization constant is: .
The state probabilities (link occupancy distribution) are:
(compare with 0.256 in the EA‐EMLM/BR) |
CC probabilities:
(compare with = = 0.256 in the EA‐EMLM/BR) |
Utilization:
b.u. (compare with 1.964 in the EA‐EMLM/BR) |
Consider a link of capacity b.u. that accommodates two elastic and two adaptive service‐classes, with the following initial traffic characteristics:
Service‐class 1: elastic, b.u., erl | Service‐class 3: adaptive, b.u., erl |
Service‐class 2: elastic, b.u., erl | Service‐class 4: adaptive, b.u., erl |
We assume that the initial offered traffic‐loads and remain constant, while and increase in steps 1.0 erl and 0.5 erl, respectively, up to final values of erl and erl. The offered traffic‐load point 1, which appears in the ‐axis of Figures 11.5–11.11, expresses the initial offered traffic‐load, while the subsequent points correspond to the increased traffic‐loads. The call service time is exponentially distributed with mean .
To achieve TC probabilities equalization among calls of all service‐classes, the BR policy is applied with the following BR parameters: and b.u.
As far as the batch size distribution is concerned, it follows the geometric distribution for all service‐classes with parameters , and , respectively. The corresponding mean batch sizes are 4, 2, 1.25, and 1.25 calls.
For the bandwidth compression mechanism, we consider three values of : (i) b.u., where no bandwidth compression takes place, and we have the BP‐EMLM/BR of [7], (ii) b.u., where bandwidth compression takes place and , and (iii) b.u., where .
The analytical and simulation results (mean values of 7 runs) of the equalized TC probabilities, , among the service‐classes for each value of T, versus the offered traffic‐load, are shown in Figure 11.5. The corresponding CC probabilities for each one of the four service‐classes are shown in Figures 11.6–11.9, respectively. Since CC probabilities refer to the total number of blocked calls out of the total number of arriving calls, there can be no BR parameters that achieve equalized CC probabilities (see also [ 7]). The analytical and simulation results of the link utilization in b.u. are presented in Figure 11.10. In all cases presented in Figures 11.5–11.9 we observe that (i) the accuracy of the analytical results is absolutely satisfactory compared to simulation results and (ii) CC and TC probabilities decrease as the value of T increases because more calls are admitted in the presence of the bandwidth compression mechanism. The analytical and simulation results of the link utilization in b.u. are presented in Figure 11.10. Since the CC and TC probabilities decrease when , the BP‐EA‐EMLM/BR achieves higher link utilization than the BP‐EMLM/BR. For further evaluation, in Figure 11.11 we present the analytical results of and CC probabilities when b.u. for the aforementioned four service‐classes (two elastic and two adaptive) as well as for two more cases: (i) all four service‐classes are of elastic type (the BP‐E‐EMLM of [ 1] is used) and (ii) all four service‐classes are of adaptive type. For presentation purposes and because simulation results are very close to the analytical results, no simulation results are provided, only the analytical results of the first and the fourth service‐classes. Figure 11.11 verifies what we intuitively expect: when all service‐classes are of elastic type, higher TC and CC probabilities are expected than in the other two cases. This is because elastic calls expand their service time when their bandwidth is compressed, and therefore remain for longer (on average) in the system than adaptive calls.
Since the batched Poisson multirate elastic adaptive loss models are a combination of the elastic adaptive multirate loss models (see Chapter 3) and the batched Poisson multirate loss models (see Chapter 10 ), the interested reader may refer to Sections 3.7 and 10.4 for possible applications.
Similar to the previous section, the interested reader may refer to the corresponding sections of Chapter 3 (Section 3.8) and Chapter 10 (Section 10.5). In addition to these sections, a possible interesting extension could be the recent work of [8]. In [ 8], a self‐optimizing 4G wireless network is considered. The network consists of a group of cells that accommodates elastic and adaptive calls of random or quasi‐random input and incorporates a mechanism for load balancing between the cells of a group. The determination of CBP is based on approximate formulas whose accuracy has been verified via simulation. The case of bursty traffic in such a network could be studied with the aid of the models in this chapter.