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Information Streams
and Traffic Processes
Professor Izhak Rubin
Electrical Engineering Department
UCLA
© 2014-2015 by Izhak Rubin
(c) Prof. Izhak Rubin 2
Arrival Point Processes (1) Messages arrive at the system in accordance with a stochastic point
process:
where An denotes the arrival time of nth message, n ≥ 1. We generally set A0=0.
Associated with the arrival process A is the arrival counting process.
where Nt ≡ N(t) denotes the arrival count at t, expressing the number of messages arriving at the system during (0, t].
(1) ,1.. ,1, 1 pwAAnAA nnn
(2) ,0 ,0, 0 NtNN t
N(t)
t A0 A1 A2 A3
1
2
0
N(t)
T2 T3 T1
(c) Prof. Izhak Rubin 3
Inter-Arrival Times and
Renewal Point Processes The inter-arrival times are denoted as
The arrival process A is typically assumed to be a Renewal point
process, under which {Tn, n ≥ 1} is a sequence of independent identically
distributed (i.i.d.) random variables. Such a process is statistically
characterized by the inter-arrival time distribution
We set A(t) = 0, for t ≤ 0.
(3) .1 ,1 nAAT nnn
(4) .tTPtA
t A0 A1 A2 A3
1
2
0
N(t)
T2 T3 T1
A4
(c) Prof. Izhak Rubin 4
Arrival Processes (2) The mean inter-arrival time is denoted as
The message arrival intensity (or rate) is given by
The arrival process is said to be a continuous-time arrival point process if A(t)
is a continuous distribution having the probability density function
a(t) = dA(t)/dt, t ≥ 0.
The arrival process is said to be a discrete-time arrival point process if A(t) is a
discrete distribution, so that arrivals can occur only at times
{tk = kσ+t0, k=0,1,2,…, }.
Slot duration = σ. We normalize the slot time, setting σ = 1. For a discrete-time
arrival process, inter-arrival times are measured in [slots], and the inter-arrival
time distribution is denoted as
)5( .TE
)6( .1
(7) .1 , jjtjTP n
(c) Prof. Izhak Rubin 5
Arrival Processes (3)
A0
A0
A1
A1
A2
A2
A3
A3
A4
A4
(a)
(b)
T1 T3
T4
t
t
Fig. 1. Realizations of (a) continuous-time and (b) discrete-time stochastic
point processes
(c) Prof. Izhak Rubin 6
Arrival Processes (4) For a continuous-time arrival point process, the Laplace
transform for the inter-arrival time p.d.f. a(t) is give by
For a discrete-time point process, the Z-transform of the inter-
arrival time probabilities {t(j), j ≥ 1} is denoted as
)8( 0)Re( ,0
*
sdttaesA st
)9( 1. ,1
*
zzjtzTj
j
(c) Prof. Izhak Rubin 7
Arrival Processes (5) For a discrete-time point process, we set Mk to denote the
number of messages arriving during the kth slot.
The associated counting process is N = {Nk, k = 0,1,2,…,} where N0=0, and
so that Nk expresses the total number of message arrivals during the first k slots.
)10( 1, ,1
kMNk
i
ik
(c) Prof. Izhak Rubin 8
Arrival Processes (6)
0
1
2
3
4
5
6
7
N(t)
t
Fig. 2. A realization of a counting process N = [N(t), t≥0]
(c) Prof. Izhak Rubin 9
Arrival Processes (7) For a discrete-time renewal point process, the
probability distribution of An is given by the
discrete-convolution
1*1 1
1
1
, 1, (15)
, and ; (16)
, 1. (17)
n
n
jn n
i
nj
n
j
P A j t j n
t j t j t j t j i t i
z P A j T z n
(c) Prof. Izhak Rubin 10
Memoryless Stochastic Point
Process
An inter-arrival time variable T is said to be memoryless, if it
satisfies
so that the residual time to next arrival is statistically independent
of the time since the last arrival.
For a memoryless distribution A(t), we obtain from the defining
identity that
, , 0 (18)P T t s T t P T s t s
(19) .0st, ,111 sAtAstA
(c) Prof. Izhak Rubin 11
Memoryless Arrival Processes
The only distributions that solve
the latter identity are given by:
1. The continuous-time exponential
distribution
2. and the discrete-time geometric
distribution.
(c) Prof. Izhak Rubin 12
Counting and Arrival Time
Distributions
where
)10( ,
1
1
1
tFtF
tAPtAP
nNPnNPnNP
nn
nn
ttt
, 1. (11)n nP A t F t n
(c) Prof. Izhak Rubin 13
Arrival Time Distribution for
Renewal Processes For a renewal point process, since
we have
where A(t)*n denotes the nth order convolution of A(t) with itself. For a continuous-time process,
and the p.d.f. is: fn(t)=a(t)*n, where a(t)*1=a(t) and Fn*(s)=[A*(s)]n.
(13) .1 ,
ntAtFn
n
(14) .1 ,)(0
1
ndssastAtA
t nn
(12) .1 ,1
nTAn
j
jn
(c) Prof. Izhak Rubin 14
Poisson Process: Definition and
Properties A Poisson process A={An, n≥0} is a Renewal point process governed by an
exponential inter-arrival time distribution:
where
is the unit step function. For the process we have
Recall that it is a unique (the only one) continuous-time renewal point process which is memoryless.
)15( 1 tUetTPtA t
)16( 0 ,0
0 ,1
t
ttU
)20( .Re ,
(19) ,
)18( ,
)17( ,
2
1
ss
sA
tUeta
TVar
TEα
t
(c) Prof. Izhak Rubin 15
Poisson Process: Arrival
Times The nth arrival occurs at time An and is governed by Erlang distribution
En,λ(t) of order n, n ≥ 1, and parameter λ > 0, and corresponding density
en,λ(t), t ≥ 0:
where the Erlang p.d.f. is given by
We have
)21(
1
0,,
n
setE
tUetAPtF
t
nn
t
nn
)22( .!1
1
, tUn
ette
tn
n
)23( . ; ;2
, n
AVarn
AEs
sE nn
n
n
(c) Prof. Izhak Rubin 16
Poisson Counting Process The counting process N={Nt, t≥0} associated with a Poisson point process is
called: Poisson counting process. The distribution of Nt can be computed by
which yields the result (showing it to be governed by a Poisson distribution):
)24( ,,1,1 tEtEtFtFnNP nnnnt
, 0,1,2,...; 0; (25)!
; t 0; (26)
; t 0. (27)
n
t
t
t
t
tP N n e n t
n
m t E N t
Var N t
(c) Prof. Izhak Rubin 17
Poisson Process as a Process with Stationary
Independent Increments The Poisson counting process N can be shown to
have independent increments, so that the number of arrivals (events) occurring over disjoint intervals are statistically independent.
Furthermore, N has stationary independent increments. An increment is said to be stationary if its distribution depends only on the length of the underlying interval and not on its actual position. Thus, we have:
,
, 0. (28)!
t s h t s
n
h
P N t s t s h n P N N n
hP N h n e n
n
(c) Prof. Izhak Rubin 18
Poisson Process as a Process with Stationary
Independent Increments (cont)
In fact, a counting process N={Nt,t≥0} can be axiomatically defined as a Poisson counting process by imposing the following requirements:
1. N0=0;
2. N has stationary independent increments;
3. Nt is governed by the Poisson distribution
, 0, 0. (29)!
n
t
t
tP N n e n t
n
(c) Prof. Izhak Rubin 19
Geometric Point Process as a
Bernoulli Point Process
The Geometric point process has the
following presentation:
Mn = number of message arrivals during the n-th
slot
{Mn,n≥1} = sequence of i.i.d. binary random
variables, so that
P(Mn = 1)=p, P(Mn = 0)=1- p, each n.
(c) Prof. Izhak Rubin 20
Realization of Geometric Point
Process
t (k) A0 A1 A2 A3
1
2
0
N(t) Nk
T2 T3
M1=1
T1
M2=0 M3=1 M4=1
3
N1=1 N2=1
N3=2
N4=3
Nk = Number of events occurring in k slots (i.e., at time t = k).
(c) Prof. Izhak Rubin 21
Geometric (Bernoulli, Binominal) Process A Geometric (Bernoulli) point process A = {An, n≥1} is a discrete-time renewal
point process for which the inter-arrival time is governed by a Geometric
distribution ( inter-arrival time T is measured in slots):
where 0 < p ≤1. We have
The arrival rate is thus equal to
1
( ) 1 , j=1,2,..., (30)j
t j P T j p p
1
1
2
( ) , 11 1
1, . (31)
PzT z z p
z p
pE T p Var T
p
1
[arrivals/slot] (32)
:
E(M) = 1 * P(M=1) + 0 * P(M=0) = P(M=1) = p [mess/slot].
pE T
Also
(c) Prof. Izhak Rubin 22
Geometric (Bernoulli, Binominal) Process:
Arrival and Counting Variables The time An of the nth arrival is governed by the z-transform [T*(z)]n, which yields
the negative-binomial distribution:
1( ) 1 , , 1, (33)
1
k nn
n
kP A k p p k n n
n
The counting process N = {Nk, k ≥ 0} is also known as a Binomial counting
process, noting that Nk = N(t) at t=k (the k-th time mark) is governed by a
Binomial distribution:
( ) 1 , 0,1,..., (33 )k nn
k
kP N n p p n k b
n