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ARTICLE IN PRESS
Contents lists available at ScienceDirect
Signal Processing
Signal Processing 90 (2010) 24–33
0165-16
doi:10.1
� Cor
E-m
fmercha
(F. Turc
(E. Griv
journal homepage: www.elsevier.com/locate/sigpro
Rayleigh fading channel simulator based oninner–outer factorization
Fernando Merchan �, Flavius Turcu, Eric Grivel, Mohamed Najim
IMS—Departement LAPS, Universite de Bordeaux 1, 351 cours de la Liberation, 33405 cedex, Talence, France
a r t i c l e i n f o
Article history:
Received 29 July 2008
Received in revised form
10 April 2009
Accepted 15 May 2009Available online 22 May 2009
Keywords:
Moving average processes
Autoregressive processes
Autoregressive moving average processes
Rayleigh fading channel
Inner–outer factorization
84/$ - see front matter & 2009 Elsevier B.V. A
016/j.sigpro.2009.05.010
responding author. Tel.: +33 5 40 00 66 74; fax
ail addresses: [email protected]
[email protected] (F. Merchan), flavius.turcu@lap
el), [email protected] (M
a b s t r a c t
The paper deals with the design of Rayleigh fading channel simulators based on the
inner–outer factorization. The core of the approach is to approximate the outer
spectral factor of the channel power spectral density (PSD) by either finite-order
polynomials or rational functions. This, respectively, leads to MA or AR/ARMA
models. The parameter estimation operates in two steps: the outer factor,
which leads to a minimum-phase filter, is first evaluated inside the unit disk
of the z-plane. Then, we propose to compute the Taylor expansion coefficients of the
outer factor because they coincide with the model parameters. Unlike other
simulation techniques, this has the advantage that the first p parameters remain
unchanged when one increases the model order from p to p+1. A comparative study with
existing channel simulation approaches points out the relevance of our ARMA model-
based method. Moreover, the ARMA model weakens the oscillatory deviations from
the theoretical PSD in the case of AR models, or low peaks at the Doppler frequencies for
MA models.
& 2009 Elsevier B.V. All rights reserved.
1. Introduction
When designing communication systems basedfor instance on CDMA techniques [1] or when conceivingnew receivers and studying their performances,channel simulation is one of the steps to be carriedout.
In an environment with no direct line-of-sight betweentransmitter and receiver, the marginal distributions of thephase and of the amplitude of the channel process areuniform and Rayleigh, respectively [2]. In addition, thetheoretical power spectral density (PSD) of the real andimaginary parts of the fading channel samples is
ll rights reserved.
: +33 5 40 00 84 06.
rdeaux.fr,
s.ims-bordeaux.fr
. Najim).
U-shaped and has two infinite peaks at the normalizedmaximum Doppler frequency �f d:
Sthðf Þ ¼
1
pffiffiffiffiffiffiffiffiffiffiffiffiffiffiffif 2
d � f 2q if f
�� �� � f d
0 elsewhere
8>><>>: (1)
while the corresponding normalized discrete-time auto-correlation function is given by the zero-order Besselfunction of the first kind:
Rtheoh ðkÞ ¼ J0ð2pf djkjÞ 8 k 2 Z (2)
Given these assumptions, various families of channelsimulators have been proposed.
For instance, Jakes’ fading model [2] based on a sum-of-sinusoids makes it possible to generate time-correlatedwaveforms. However, as independent channels cannot beeasily simulated with this model, Dent et al. [3] propose toweight the sinusoids by orthogonal random codes such as
ARTICLE IN PRESS
F. Merchan et al. / Signal Processing 90 (2010) 24–33 25
Hadamard ones. In [4], Pop and Beaulieu report that Jakes’simulator is wide-sense nonstationary and hence, proposea modified simulator by adding random phases in the low-frequency oscillators. Nevertheless, in this simulator, theautocorrelation and the cross-correlations of the quad-rature components fail to match the desired propertieseven when the number of sinusoids tends to infinity [5].Therefore, Zheng and Xiao [6] propose a new simulatorthat introduces randomness to the path gain, the Dopplerfrequency and the initial phase of the sinusoids. Inaddition, the authors proved that the second-orderstatistics of this simulator could correspond to the desiredones.
As an alternative, filtering-based approaches can beconsidered:
On the one hand, the filter can be designed in thefrequency-domain. Thus, in [7], the author combines afiltering step and an inverse discrete Fourier transform(IDFT). Although Young and Beaulieu [8] manage toreduce the computational cost of this approach, allsamples have to be generated by using a single fastFourier transform. Due to the IDFT, this off-line simulationrequires large memory storage.
On the other hand, the filtering can be carried out inthe time-domain. This is the case of simulators based onAutoregressive Moving Average ARMA, AutoRegressive(AR) or Moving Average (MA) models. This approachmay be a priori questionable. Indeed, as the PSD of thereal and imaginary parts is bandlimited, the channelprocess should be deterministic, according to the Kolmo-gorov–Szego formula.1 However, unlike the sum-of-sinu-soids methods, since the linear stochastic models arequite simple and few parameters have to be estimated,these approaches are very popular both for channelsimulator design and Kalman-filter based receiver designin mobile communication system. Thus, in [9], the transferfunction associated to the ARMA model corresponds to a3rd order Butterworth low-pass filter. Nevertheless,choosing this kind of filter leads to a poor approximationof the channel properties. In [10] and [11], an ARMAprocess followed by a multistage interpolator is consid-ered. The authors in [10] report that this combinationmakes it possible to select low orders for the ARMAprocess. Nevertheless, only a very high down-samplingfactor can lead to a PSD which is never equal to zero andhence allows the simulated channel to match thetheoretical channel properties.
In various papers including [12] and [13], the authorssuggest using a pth order AR process because it cangenerate at most p resonances in the PSD [13]. However,when selecting a 2nd order AR model whose parametersare obtained by solving the Yule–Walker equations, thetwo PSD peaks are located at �f d=
ffiffiffi2p
instead of �f d [13].This factor 1=
ffiffiffi2p
is justified by comparing the Taylorseries expansions of both the theoretical autocorrelationfunction Rtheo
h ðkÞ and the 2nd order AR process. When theAR order is higher than 2, the channel autocorrelation
1 s2 ¼ exp½R 1=2�1=2 ln Sðf Þdf � where Sðf Þ denotes the PSD of the process
sðnÞ and s2 is the error variance of the optimal predictor of sðnÞ.
matrix used in the Yule–Walker equations becomes ill-conditioned [13]. To overcome this problem, Baddour andBeaulieu [12] suggest adding a very small bias s2 in themain diagonal of the autocorrelation matrix of thechannel (e.g., s2 ¼ 10�7 for f d ¼ 0:01). This leads tomodeling the channel by the sum of the theoretical fadingprocess and a zero-mean white process with variance s2
and hence makes the PSD of the process log-integrable.In [14], the authors model the channel by a finite-order
moving average process. The MA parameter estimationconsists in designing a FIR filter by means of the windowmethod. Indeed, the impulse response coefficients,namely the MA parameters, are estimated by first takingthe inverse Fourier transform of the square root of thetheoretical PSD of the channel, by windowing it and thenby shifting it in time. However, the first p MA parameterschange when increasing the model order from p to p+1.Durbin’s method [15], which is a standard estimationtechnique, can be also considered to estimate the MAparameters. Since this method turns the MA parameterestimation issue into a set of two of AR parameterestimation problems, the channel autocorrelation matrixused in the Yule–Walker equations may be ill conditioned.Hence, Baddour’s ad-hoc solution [12] must be consid-ered. In addition, like Verdin’s approach [14], the selectionof the model order has to be addressed.
To compensate for the drawbacks of the aboveapproaches, Grolleau et al. [17] recently suggest using asinusoidal stochastic model; it corresponds to a filteredversion of a sum of two sinusoids in quadrature at themaximum Doppler frequency and whose amplitudes areAR processes. Nevertheless, the estimation of the ARparameters is not necessarily straightforward and requiresmetaheuristics such as Genetic Algorithms when themaximum Doppler frequency is lower than 1=2p.
In this paper, to estimate the channel model para-meters and select the model order, we propose to considerthe inner–outer factorization, which has been used so farin information theory, system theory, control and filterdesign [16]. Thus, when dealing with MA modeling, thecorresponding transfer function can be expressed as theproduct of:
(1)
the inner function which can be seen as an all-passfilter;(2)
the outer function which is causal and has its zeroes inthe closed unit disk in the z-plane; hence, thiscorresponds to a minimum-phase filter. In addition,the square absolute value of the outer function on theunit circle in the z-plane equals the theoretical PSD ofthe channel. Furthermore, among all functions whichhave the same absolute value on the unit circle in thez-plane, the outer function is the one with the largestabsolute value outside the unit disk.In the following, we first suggest using an infinite-
order MA model whose transfer function coincides withits outer function. Since finite-order models are ratherconsidered in practical case, the approach we proposemakes it possible to tune the upper bound of the error, inabsolute value, between the theoretical PSD and theARTICLE IN PRESS
F. Merchan et al. / Signal Processing 90 (2010) 24–3326
simulated one. This tuning leads to the definition of acriterion for the model order selection. In addition, withour method, the first p parameters are unchanged whenincreasing the model order from p to p+1. It should benoted that our approach is also adapted to AR and ARMAmodels.
The remainder of the paper is organized as follows:Section 2 presents the proposed approach to estimate themodel parameters. In Section 3, the method is derived forthe MA, AR and ARMA models. It also presents how toselect the model order for MA and AR models. Section 4describes the numerical implementation of the estimationmethod. In Section 5, a comparative study illustrates thebenefits of the proposed ARMA methods with respect tothe methods presented in [12,14,15,17]. Conclusions arepresented in Section 6.
2. Mathematical overview of the method
Let xðnÞ be a real regular process and Pðf Þ denote itsPSD. It is known that, whenever Pðf Þ is log-integrable, theprocess PSD can be factored as follows:
Pðf Þ ¼ jHðzÞj2jz¼expðj2pf Þ ¼ HðzÞH�ðzÞjz¼expðj2pf Þ (3)
for causal functions HðzÞ ¼Pþ1
k¼0bkz�k. The functions HðzÞ,called spectral factors of Pðf Þ, can also be seen as thetransfer functions of a system driven by a zero-meanwhite noise, with output xðnÞ.
In the following we will rather deal with causalfunctions of z instead of z�1, in order to fit into the settingof Hardy spaces [18]. Therefore, instead of HðzÞ, we willconsider the spectral factors:
FðzÞ ¼Xþ1k¼0
bkzk (4)
It also satisfies (3) as long as fbkgk�0 are real, since
jHðzÞj2 ¼ jFðz�1Þj2 ¼ jF�ðzÞj2 for z ¼ expðj2pf Þ (5)
A spectral factor FðzÞ is not unique in general; they are allof the type [18]:
FðzÞ ¼ UðzÞF0ðzÞ (6)
where U is any inner function, i.e. jUðzÞjz¼expðj2pf Þ ¼ 1, andF0 is the unique outer function satisfying (3). For the sakeof simplicity, we consider the particular case whereUðzÞ ¼ 1, meaning that the spectral factor F is outer.According to (6), selecting any other function will onlyaffect the argument of HðzÞ.
The estimation methods we propose operate in two steps:
(1)
Estimation of outer the factor F0: the factor F0 iscomputed on a circle of radius ro1 in the z-plane bymeans of the following Poisson kernel representation:F0ðrej2puÞ ¼ exp
Z 1=2
�1=2
1
2ð2pÞ1þ rej2pðu�f Þ
1� rej2pðu�f Þ
� �log jPðf Þjdf
(7)
(2)
Estimation of the coefficients fbkgk�0: according to (6),the outer function can be expressed either in termsof the coefficients fbkgk�0 or by using the Taylorseries.
F0ðzÞ ¼ F0ð0Þ þFð1Þ0 ð0Þ
1!zþ � � � þ
FðnÞ0 ð0Þ
n!zn þ � � � ¼
Xþ1k¼0
bkzk
(8)
Hence, by using the Cauchy formula on the circle ofradius r in the z-plane, the coefficients fbkgk�0 can beobtained as follows:
bk ¼FðkÞ0 ð0Þ
k!¼
1
rk
Z 2p
0F0ðrej2puÞe�jk2pu du 8 k 2 N (9)
Since Pðf Þ is integrable, the coefficients bk
� �k�0
arenecessarily square summable, meaning that thefinite-order polynomials
FpðzÞ ¼Xp
k¼1
bkzk (10)
converge to F0 in the L2 norm when p!þ1.
The methods we propose in the remainder of the paperdeal with three types of finite-order approximations of thespectral factor F0 and lead to MA, AR and ARMA models:
(1)
The pth order MA model, denoted MA(p), is the moststraightforward and corresponds to the estimation ofFp in (10)(2)
A pth order AR model, denoted AR(p), is obtained byapplying the above finite-order estimation to theinverse of Pðf Þ.(3)
An ARMA model of order p and q, denoted ARMA(p,q),model is derived by approximating F0 with rationalfunctions of order ðp;qÞ:Fp;qðzÞ ¼
Ppk¼0bkz�k
1þPq
k¼0akz�k(11)
The following sections describe each approach andhow to implement them in practical cases.
3. Inner–outer factorization for MA, AR and ARMAchannel modeling
3.1. MA model for Rayleigh channel simulator
Let xðnÞ be an infinite-order MA process defined asfollows:
xðnÞ ¼Xþ1k¼0
bkuðn� kÞ (12)
where fbkgk�0 are the real MA parameters and uðnÞ is a zero-mean white noise sequence with unit variance. If xðnÞ has itsPSD equal to the channel’s theoretical power spectral densitySth, the corresponding transfer function HðzÞ ¼
Pþ1k¼0bkz�k
satisfies:
Sthðf Þ ¼ jHðzÞj2jz¼expðj2pf Þ (13)
Since parameters fbkgk�0 are real, we can rewrite (5) asfollows:
jHðzÞj2 ¼ jFðz�1Þj2 for z ¼ expðj2pf Þ (14)
ARTICLE IN PRESS
2 This choice of modified PSD for the AR model is due to the
difficulty of dealing with very large values of the inverse of the PSD. In
Section 4, this modified PSD is compensated by filtering the resulting AR
process by a low-pass filter.
F. Merchan et al. / Signal Processing 90 (2010) 24–33 27
Following the approach presented in the previous section, thefunction FðzÞ can be expressed as the product of its inner andouter factors. Taking the same assumption as above, i.e. theinner factor equal to 1, the MA parameters fbkgk�0 coincidewith the coefficients of the Taylor series of the outer functionof FðzÞ.
We propose to estimate the outer function FðzÞ and theMA parameters by using, respectively, (7) and (9).
However, to use (7) the PSD must be log-integrable, i.e.,the PSD cannot be bandlimited. This is not the case of thetheoretical channel PSD Sth
ðf Þ. In [13], the authors takeinto account that issue by adding a white noise of variances2 to the original process. Here, we also slightly modifythe channel PSD and express it as the product of twofactors defined as follows:
SUðf Þ ¼
1
pffiffiffiffiffiffiffiffiffiffiffiffiffiffiffif 2
d � f 2q if jf j � f d
1 elsewhere
8>><>>: (15)
and
Sflatðf Þ ¼
1 if jf j � ð1þ xÞf d
� elsewhere
�(16)
where the parameter � guarantees the log-integrabilitycondition whereas x allows the compensation of the offsetof the frequency peaks at f d. In counterpart, it affects thedecay of the PSD at f d. In the following, Fmod
0 denotes theouter function computed with (7) where Pðf Þ is replacedby the modified PSD, namely SUSflat.
In practical case, a truncated version of the MA modelFpðzÞ ¼
Ppk¼0bkzk is considered. In order to estimate the
modeling error we will use the L2 norm on the unit circle,i.e.
J ¼
Z p
�pjSthðejyÞ � jFpðe
jyÞj2jdy where ejy ¼ ej2pf (17)
Note that Fp also depends on �. It is clear that Fp does notconverge to Sth, since Fp converges to � outside½e�j2pf d ; ej2pf d � while Sth is zero on this interval. However,given a prescribed error d0, one can choose both � and p
such that Jod0. We indicate here how one can calculate anupper bound of the modeling error for a given order p.However, we do not address the question of selecting anoptimal order for a given modeling error.
The error J can be upper-bounded as follows:
J �
Z p
�pjSthðejyÞ � jFmod
0 ðejyÞj2jdy
þ
Z p
�pjjFmod
0 ðejyÞj2 � jFpðe
jyÞj2jdy (18)
According to Eqs. (1), (15) and (16), the first term in theinequality above is equal to 2p�ð1� 2f dÞ, while, thesecond satisfies:
Z p
�pjjFmod
0 ðejyÞj2 � jFpðe
jyÞj2jdy
�
Z p
�pjFmod
0 ðejyÞ2 � Fpðe
jyÞ2jdy
¼
Z p
�pjFmod
0 ðejyÞ � FpðejyÞj � jFmod
0 ðejyÞ þ FpðejyÞjdy
�
ffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiZ p
�pjFmod
0 ðejyÞ � FpðejyÞj2 dy
s ffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiZ p
�pjFmod
0 ðejyÞ þ FpðejyÞj2 dy
s
�
ffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiE2�Xp
k¼0
jbkj2
vuutffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiXp
k¼0
4jbkj2 þ
Xþ1k¼pþ1
jbkj2
vuut
� 2E
ffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiE2�Xp
k¼0
jbkj2
vuut (19)
where E ¼R p�p jF
mod0 ðe
jyÞj2 dy ¼ 2pð1þ �ð1� 2f dÞÞ.So, one has:
J � 2p�ð1� 2f dÞ þ 2E
ffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiE2�Xp
k¼0
jbkj2
vuut (20)
At that stage, given a prescribed error boundd042p�ð1� 2f dÞ, there is always a minimum value forthe model order p that satisfies:
0oE2�Xp
k¼0
jbkj2oðd0 � 2p�ð1� 2f dÞÞ
2ð2EÞ�2 (21)
In the next section, the approach for the case of ARprocesses is presented.
3.2. AR model for Rayleigh channel simulator
Let us now consider the infinite-order AR process xðnÞ
defined by:
xðnÞ ¼ �Xþ1k¼0
akxðn� kÞ þ uðnÞ (22)
In that case, FARðzÞ ¼
Pþ1k¼0akzk verifies:
Sthðf Þ ¼ jHðzÞj2jz¼expðj2pf Þ ¼
1
jFARðz�1Þj2
�����z¼expðj2pf Þ
(23)
To evaluate the outer function of FARðzÞ and the AR
parameters, Pðf Þ is replaced by 1=Sthðf Þ in Eq. (7). Then, the
AR parameters can be estimated by using the methoddescribed in Section 2 based on (9).
In addition, the modified2 PSD is equal to SUðf Þ.
Furthermore, one can calculate an upper bound of themodeling error G for a AR model of order q 1=FqðzÞ ¼
1=Pq
k¼0akzk as follows:
G ¼
Z 2pf d
�2pf d
j1=SthðejyÞ � jFqðe
jyÞj2jdy where ejy ¼ ej2pf
�
Z p
�pjjFmod
0 ðejyÞj2 � jFqðe
jyÞj2jdy
�
ffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiW2�Xq
k¼0
jakj2
vuut 2W (24)
where W ¼R p�p jF
mod0 ðe
jyÞj2 dy ¼ p3f 2d þ 2pð1� 2f dÞ.
ARTICLE IN PRESS
Table 1Evaluation of error Jd and quality measures Gmean and Gmax for various simulators.a
Number of parameters Jd Gmean ðdBÞ Gmax ðdBÞ
f d ¼ 0:01 f d ¼ 0:05 f d ¼ 0:01 f d ¼ 0:05 f d ¼ 0:01 f d ¼ 0:05
50
Proposed ARMA 0.8826 0.2495 1.0483 0.4397 1.1128 0.4556
ARMA (window meth.)b 0.5698 0.2164 1.0712 0.3994 1.1334 0.4208Proposed AR 0.6979 0.3318 10.3672 6.3017 10.4001 6.3171
Baddour AR [12] 0.5570 0.6317 1.5935 2.4487 1.7659 2.6832
Proposed MA 0.9764 0.4263 4.0557 6.1530 4.2903 6.4728
Verdin MA [14] 0.6040 0.3591 3.2063 3.0014 3.4206 3.1852
Durbin MA [15] 0.9859 0.4961 4.6373 10.4704 4.8668 10.7523
SS [17] 0.7652 0.4132 3.7491 0.7306 3.7874 0.8953
120
Proposed ARMA 0.4116 0.1251 0.5989 0.1680 0.6163 0.1735
ARMA (window meth.)b 0.2805 0.1173 0.3679 0.1592 0.4056 0.1643Proposed AR 2.6900 0.3014 16.6011 6.0031 16.7239 6.0468
Baddour AR [12] 0.8008 0.3382 2.1303 0.7204 2.3946 0.7940
Proposed MA 0.6435 0.2960 7.5843 3.9450 7.8907 4.1729
Verdin MA [14] 0.5307 0.3428 3.0998 2.0063 3.3135 2.1541
Durbin MA [15] 0.8234 0.3762 8.4128 9.4176 8.6786 9.7032
300
Proposed ARMA 0.2303 0.0664 0.2785 0.0515 0.3450 0.0538ARMA (window meth.)b 0.1533 0.0685 0.0617 0.0581 0.2624 0.0609
Proposed AR 1.7068 0.2889 14.6827 5.6942 14.7964 5.7240
Baddour AR [12] 0.5695 0.2475 0.5434 0.1830 0.7038 0.2514
Proposed MA 0.4308 0.1718 5.1412 1.4344 5.4138 1.5508
Verdin MA [14] 0.3831 0.1963 1.9042 0.9865 2.0559 1.0713
Durbin MA [15] 0.5850 0.2489 11.8706 7.4949 12.1374 7.7233
a For MA(p) and AR(p) models the number of parameters is the order p. For ARMA (p, q) models the number of parameters is p+q. For the proposed
simulator, we set: N ¼ 4096. In addition, L ¼ 131 072 and D ¼ 1024.b See Remark in II.C.
0.046 0.048 0.050
10
20
30
40
50
60
normalized frequencies0.046 0.048 0.05
0
10
20
30
40
50
60
normalized frequencies
Theoretical PSD
Proposed MA (1000)Durbin-MA (1000) [15]
Theoretical PSD
Proposed MA (1000)Verdin-MA (1000) [14]
Fig. 1. PSD of MA-based simulators with f d ¼ 0:05.
F. Merchan et al. / Signal Processing 90 (2010) 24–3328
ARTICLE IN PRESS
0.03 0.035 0.04 0.045 0.050
10
20
30
40
50
60
70
80
90
100
110
normalized frequencies
Theoretical PSDProposed ARMA (2,48)Komninakis ARMA [11]
Fig. 3. PSD of simulators with f d ¼ 0:05 and 50 parameters.
F. Merchan et al. / Signal Processing 90 (2010) 24–33 29
Therefore, by considering a prescribed bound r040,the model order q can be chosen such as:
0oW2�Xq
k¼0
jakj2or0ð2WÞ�2 (25)
In the next section, we consider the case of ARMAprocesses.
3.3. ARMA model for Rayleigh channel simulator
Let us now consider the ARMA process xðnÞ defined by:
xðnÞ ¼ �Xq
k¼1
akxðn� kÞ þXþ1k¼0
bkuðn� kÞ (26)
The corresponding transfer function:
HðzÞ ¼
Pþ1k¼0bkz�k
1þPq
k¼1akz�k¼
BðzÞ
AðzÞ(27)
satisfies: jHðzÞjjz¼expðj2pf Þ ¼ Sthðf Þ.
Given (1), we propose to define denominator AðzÞ as asecond-order polynomial with roots equal to re�j2pf d , withr close, but inferior to 1. Therefore, the numerator BðzÞ canbe defined as follows:
jBðzÞj2jz¼expðj2pf Þ ¼ Sthðf ÞjAðzÞj2jz¼exp j2pfð Þ (28)
To evaluate the outer function of Bðz�1Þ, Pðf Þ in Eq. (7) isreplaced by the right side of Eq. (28). Then, the parametersfbkgk�0 can be estimated by using the method presented inSection 2 based on (9).
Moreover, since a finite polynomial approximation ofthe outer factor of BðzÞ has no roots equals to re�j2pf d , theresulting transfer function still admits two poles equal tore�j2pf d . This leads to a better fitting of the model PSD in asmall neighborhood of Doppler frequencies.
Remark. An alternative way to estimate the MAparameters of this ARMA model consists in using thewindow method for the design of FIR filters, as used in
0.034
0.036
0.038 0.0
40.0
420.0
440.0
460.0
48 0.05
0.052
0
50
100
150
normalized frequencies
Theoretical PSDProposed ARMA (2,298)Baddour AR (300) [12]
Fig. 2. PSD of simulators with f d ¼ 0:05 and 300 parameters.
[14] for a MA model. Thus, we also propose to obtain theMA parameters by first taking the inverse Fourier trans-form of the square root of the right side of Eq. (28), bywindowing it and then by shifting it in time.
The purpose of the next section is to estimate the outerfunction and its Taylor coefficients, in practical cases.
4. Implementation
To illustrate the way the simulation method can beimplemented, let us consider the MA model for the sake ofsimplicity.
Since the integrand in (7) cannot be computedanalytically, we suggest estimating the values of the outerfunction for a finite number of points on a circle of radiusro1 in the z-plane.
For this purpose, let us introduce N values of thediscrete PSD SU
ðm=NÞ:
SUðm=NÞ ¼
1 m ¼ �N=2; . . . ;�md � 1
1
pf d
mdp2� arcsin
md � 1
md
� �� �m ¼ �md
1
pf d
ffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiffiffi1� ðm=mdÞ
2q �md þ 1 � m � md � 1
1
pf d
mdp2� arcsin
md � 1
md
� �� �m ¼ md
1 m ¼ md þ 1; :::;N=2� 1
8>>>>>>>>>>>>>><>>>>>>>>>>>>>>:
(29)
where md ¼ f dN
is the largest frequency index that doesnot exceed the maximum Doppler frequency. The re-sponse for m ¼ md is chosen such that the area under aninterpolation of the spectrum coefficients is equal to thearea under the continuous-time spectrum curve given in(1), as shown in [8].
Given f d, N must be chosen high enough so that thediscrete version of the PSD can be relevant. Then, for agiven radius r, the outer function FU of SU can becomputed by using the discrete version of the Poisson
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F. Merchan et al. / Signal Processing 90 (2010) 24–3330
integral formula (7) for �N=2 � noN=2:
FUðn=NÞ ¼ exp
XN=2�1
m¼�N=2
1
2N
1þ rej2pðn�mÞ=N
1� rej2pðn�mÞ=N
� �logðSU
ðm=NÞÞ
24
35
¼ exp1
2N
1þ rej2pn=M
1� rej2pn=M
� �� logðSU
ðn=NÞÞ
� �(30)
where * denotes the convolution.Thus, (30) can be implemented through a fast
convolution algorithm [19]. Moreover, the outer function
0.03 0.035 0.04 0.045 0.050
10
20
30
40
50
60
70
normalized frequencies
10
10
10
1
Theoretical PSDProposed ARMAARMA (window meth.)
Fig. 5. PSD of proposed ARMA methods with f d ¼ 0:05 an
0.03 0.035 0.04 0.045 0.050
10
20
30
40
50
60
70
80
90
100
110Theoretical PSDProposed ARMA (2,48)SS (50) [17]
Fig. 4. PSD of simulators with f d ¼ 0:05 and 50 parameters.
Fflat of Sflat is expressed by:
Fflatðn=NÞ ¼ exp
Z 1=2
f¼�1=2
1
2ð2pÞ1þ rej2p n=N�fð Þ
1� rej2p n=N�fð Þ
!log jSflat
ðf Þjdf
(31)
To calculate the Taylor coefficients, the following discreteversion of Eq. (9) is considered:
bðkÞ ¼1
Nrk
XN�1
n¼0
FUðn=NÞ � Fflat
ðn=NÞe�j2nkðn=NÞ (32)
0 0.1 0.2 0.3 0.4
-15
-10
-5
00
normalized frequencies
Theoretical PSDProposed ARMAARMA (window meth.)
d 120 parameters in linear and logarithmical scale.
0 100 200 300 400 500 600 700 800 900 1000-0.5
0
0.5
1
Lag
TheoryBaddour AR(120) [12]Proposed ARMA (2,118)
Fig. 6. Autocorrelation functions for methods with f d ¼ 0:01 and 120
parameters.
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Table 2Values of pole modulus r for the proposed ARMA simulator.
Number of parameters f d Poles modulus r minimizing criteria
Jd D ¼ 200 D ¼ 512 D ¼ 1024
Gmean Gmax Gmean Gmax Gmean Gmax
50 0.05 0.99410 0.99280 0.99270 0.99330 0.99330 0.99370 0.99380
0.10 0.99240 0.99170 0.99160 0.99230 0.99240 0.99290 0.99300
0.15 0.99140 0.99100 0.99100 0.99190 0.99200 0.99250 0.99260
120 0.01 0.99780 0.99695 0.99690 0.99705 0.99700 0.99715 0.99715
0.05 0.99700 0.99645 0.99640 0.99665 0.99665 0.99685 0.99685
0.10 0.99630 0.99600 0.99600 0.99630 0.99625 0.99655 0.99660
0.15 0.99580 0.99100 0.99560 0.99605 0.99605 0.99640 0.99645
300 0.01 0.99905 0.99885 0.998800 0.99880 0.99875 0.99880 0.99880
0.05 0.99880 0.99865 0.998650 0.99860 0.99860 0.99870 0.99865
0.10 0.99920 0.99920 0.99920 0.99915 0.99910 0.99910 0.99910
0.15 0.99910 0.99905 0.999050 0.99910 0.99910 0.99915 0.99910
Table 3Effect of parameter N in the proposed methods.a
Method N J Gmean ðdBÞ Gmax ðdBÞ
Proposed ARMA 4096 0.1251 0.1680 0.1735
2048 0.1231 0.1652 0.1705
1024 0.1211 0.1627 0.1676
512 0.1321 0.1766 0.1811
256 0.1815 0.2495 0.2545
128 0.4990 0.6878 0.6958
Proposed MA 4096 0.2960 3.9450 4.1729
2048 0.2962 3.8539 4.0793
1024 0.2966 3.6969 3.9179
512 0.3093 3.7416 3.9663
256 0.3473 4.0266 4.2646
128 0.5931 4.0372 4.2639
Proposed AR 4096 0.3014 6.0031 6.0468
2048 0.3111 5.7253 5.7676
1024 0.3340 5.2206 5.2599
512 0.4077 6.9288 6.9754
256 0.7342 10.7168 10.7601
128 0.7063 8.0198 8.0408
a With f d ¼ 0:05 and number of parameters 120.
3 Simulations showed that when ro0:965 and r40:998, the square
of the absolute value of the estimated transfer function diverges from the
theoretical PSD.
F. Merchan et al. / Signal Processing 90 (2010) 24–33 31
It should be noted that (32) can be implemented as aweighted FFT of FU
ðn=NÞ � Fflatðn=NÞ.
Therefore, the algorithm requires OðN log NÞ operations.
Remark 1. When dealing with AR modeling, SUðm=NÞ is
replaced by its inverse in eq. (30) and only FUðn=NÞ is
considered in Eq. (32). Furthermore, a low-pass filteringstage is added. The L-length impulse response pðnÞ isdefined by:
pðnÞ ¼ 2f d
sinð2pðn� L=2Þf dÞ
2pðn� L=2Þf d
(33)
where L is high enough to weaken Gibb’s oscillations atdiscontinuities in the frequency domain.
Remark 2. In the case of ARMA models, SUðm=NÞ is
replaced by the product SUðm=NÞjAðzÞj2jz¼expðj2pm=NÞ in (30).
5. Comparative study
In this section, we compare the proposed simulatorswith:
(1)
the AR-based simulator [12], (2) the MA-based simulator given in [14], (3) Durbin’s method for MA parameter estimation [15]and,
(4) the stochastic sinusoidal (SS) model simulator [17].For the channel simulators we present in this paper, theparameter r is assigned3 to 0.98 whereas � and x are set to0.0125 and 0.025, respectively. These values are chosenexperimentally for a compromise between the maximumDoppler frequency offset and the PSD decay. For theARMA-based model, different values of the pole modulus,namely r, is chosen in each scenario.
To compare the various simulators, we introduce threecriteria. The first criterion is the mean error Jd defined asfollows:
Jd ¼1
L
XL=2�1
n¼�L=2
jSthðn=LÞ � jHðn=LÞj2j (34)
The second and third criteria are two quality measures,used for instance in [8,12]. The mean power andmaximum power margins Gmean and Gmax are defined by:
Gmean ¼1
s2XD
tracefCXC�1
X CXg (35)
Gmax ¼1
s2X
maxfdiagfCXC�1
X CXgg (36)
where CX and CX are the D D covariance matrices of thetheoretical channel and the simulated channel processes,
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0.044 0.046 0.048 0.050
10
20
30
40
50
60
70
0.044 0.046 0.048 0.050
10
20
30
40
50
60
70
Theory
N = 4096N = 2048
N = 1024
Theory
N = 512N = 256
N = 128
Fig. 7. PSD of ARMA method for different values of N with f d ¼ 0:05 and 120 parameters.
F. Merchan et al. / Signal Processing 90 (2010) 24–3332
respectively, and s2X is set to unity in this case. These
measures are given in dB (i.e. GdB¼ 10 log 10ðGÞ). Thus,
perfect performance corresponds to 0 dB for both mea-sures. Note that Gmean and Gmax measure the similarity ofthe theoretical and the simulated autocorrelation function(ACF) whereas the error Jd evaluates the differencebetween the theoretical and the simulated PSD. Thereader is referred to [20] for more information aboutthese criteria.
According to various tests we carried out and givenTable 1 and Fig. 1, the proposed MA-based method andVerdin simulator [14] provide close results and outper-forms Durbin-based method [15].
According to Table 1 and Figs. 2, 3 and 4, the ARMA-based proposed approaches, i.e. using inner–outer factor-ization and using the window method, outperform theother solutions. More particularly, in Fig. 2, the PSDobtained with the ARMA (2,298) is very close to thetheoretical PSD both in low frequencies and in theneighborhood of the Doppler frequency whereas Bad-dour’s AR-based approach4 shows important oscillationsin the range ð�f d; f dÞ and has a maximum peak offset atDoppler frequency.
According to Fig. 5, the PSD of both ARMA-basedproposed approaches are very close to each other forf � f d. For f4f d the PSD of the approach using thewindow method has values closer to the theoreticalPSD than the PSD of the approach using inner–outerfactorization.
4 The AR-based approach requires Oðp2Þ operations when using
Levinson recursion [21].
According to Fig. 6, the ACF of Baddour’s AR processpresents important deviations from theoretical ACF,especially for lags superior to the order of the model.The ACF the proposed ARMA-based approach presentssmaller differences from the theoretical one.
The SS approach was tested for the case of 50parameters. It leads to the second best performance5 forf d ¼ 0:05.
To choose the root modulus, namely r, for theproposed ARMA-based approach, we have tested valuesvarying from 0.9910 to 0.99990 with step of 5 10�5.Table 2 presents the values minimizing the error criterionJd and quality measures Gmean and Gmax for different valuesof f d and different number of parameters.
As mentioned in Section 4, the number of samples N ofthe discrete PSD used in the proposed methods must bechosen high enough. For instance, we consider theproposed simulators with f d ¼ 0:05 and 120 parameters.According to Table 3 and Figs. 7 and 8, we obtain veryclose results when setting N to f4096;2048;1024 or 512g.For No512, the difference with respect to the theoreticalPSD clearly increases.
6. Conclusions
In this paper, we have investigated the relevance ofinner–outer factorization for Rayleigh fading channelsimulator. We have proposed a new method to estimatethe model parameters of AR, MA and ARMA models. The
5 Given the frequencies tested, i.e.: f d ¼ f0:01;0:05g, genetic algo-
rithms were used to estimate the AR parameters.
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0.01 0.02 0.03 0.04 0.050
2
4
6
8
10
12
14
16
18
20
0.01 0.02 0.03 0.04 0.050
2
4
6
8
10
12
14
16
18
20
Theory
N = 4096N = 2048
N = 1024
Theory
N = 512N = 256
N = 128
Fig. 8. PSD of MA method for different values of N with f d ¼ 0:05 and 120 parameters.
F. Merchan et al. / Signal Processing 90 (2010) 24–33 33
comparative study we have carried out confirms that ourARMA-based simulator outperforms the other approaches.
Acknowledgements
This work was partially supported by the FrenchMinistry of Foreign Affairs and the National Bureau ofScience, Technology and Innovation of Panama (SENACYT).
References
[1] G.L. Stuber, Principles of Mobile Communications, Kluwer, Boston,MA, 2001.
[2] W.C. Jakes (Ed.), Microwave Mobile Communications, IEEE Press,Wiley, 1974.
[3] P. Dent, G.E. Bottomley, T. Croft, Jakes’ fading model revisited,Electron. Lett. 29 (3) (June 1993) 1162–1163.
[4] M.F. Pop, N.C. Beaulieu, Limitations of sum-of sinusoids fadingchannel simulators, IEEE Trans. Commun. 49 (April 2001) 699–708.
[5] C. Xiao, Y.R. Zheng, N.C. Beaulieu, Second-order statistical propertiesof the WSS Jakes’ fading channel simulator, IEEE Trans. Commun. 50(June 2002) 888–891.
[6] Y.R. Zheng, C. Xiao, Simulation models with correct statisticalproperties for Rayleigh fading channels, IEEE Trans. Commun. 51(June 2003) 920–928.
[7] J.I. Smith, A computer generated multipath fading simulation formobile radio, IEEE Trans. Veh. Technol. 24 (August 1975) 39–40.
[8] D.J. Young, N.C. Beaulieu, The generation of correlated Rayleighrandom variates by inverse Fourier transform, IEEE Trans. Commun.48 (7) (July 2000) 1114–1127.
[9] C. Loo, N. Secord, Computer models for fading channels withapplications to digital transmission, IEEE Trans. Veh. Technol. 40 (4)(November 1991) 700–707.
[10] D. Schafhuber, G. Matz, F. Hlawatsch, Simulation of widebandmobile radio channels using subsampled ARMA models andmultistage interpolation, IEEE-SSP (August 2001) 571–574.
[11] C. Komninakis, A fast and accurate Rayleigh fading simulator, IEEEGLOBECOM ‘03 6 (December 2003) 3306–3310.
[12] K.E. Baddour, N.C. Beaulieu, Autoregressive modeling for fadingchannel simulation, IEEE Trans. Commun. 4 (4) (July 2005)1650–1662.
[13] H. Wu, A. Duel-Hallen, Multiuser detectors with disjoint Kalmanchannel estimators for synchronous CDMA mobile, IEEE Trans.Commun. 48 (5) (May 2000) 752–756.
[14] D. Verdin, T.C. Tozer, Generating a fading process for the simulationof land-mobile radio communications, Electron. Lett. 29 (23)(November 1993) 2011–2012.
[15] J. Durbin, Efficient estimation of parameters in moving averagemodels, Biometrika 46 (1959) 306–316.
[16] P. Dewilde, A.J. van der Veen, Time-Varying Systems and Computa-tions, Kluwer Academic Publishers, Boston, 1998.
[17] J. Grolleau, E. Grivel, M. Najim, Two ways to simulate a Rayleighfading channel based on a stochastic sinusoidal model, IEEE SignalProc. Lett. 15 (2008) 107–110.
[18] K. Hoffman, Banach Spaces of Analytic Functions, Prentice-Hall,Englewood Cliffs, NJ, 1962.
[19] V.K. Madisetti, D.B. Williams, The Digital Signal Processing Hand-book, CRC Press, Boca Raton, 1998.
[20] D.J. Young, N.C. Beaulieu, Power margin quality measures forcorrelated random variates derived from the normal distribution,IEEE Trans. Inf. Theory 49 (1) (July 2003) 241–252.
[21] C.W. Therrien, Discrete Random Signals and StatisticalSignal Processing, Prentice-Hall, Englewood Cliffs, New Jersey,1992.