# Convergence Results for the Gaussian Mixture Implementation of the Extended-Target PHD Filter and Its Extended Kalman Filtering Approximation

Authors: Feng Lian; Chongzhao Han; Jing Liu; Hui Chen
Journal: Journal of Applied Mathematics
 (2012)

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## Abstract

The convergence of the Gaussian mixture extended-target probability hypothesis density (GM-EPHD) filter and its extended Kalman (EK) filtering approximation in mildly nonlinear condition, namely, the EK-GM-EPHD filter, is studied here. This paper proves that both the GM-EPHD filter and the EK-GM-EPHD filter converge uniformly to the true EPHD filter. The significance of this paper is in theory to present the convergence results of the GM-EPHD and EK-GM-EPHD filters and the conditions under which the two filters satisfy uniform convergence.


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## Body

## 1. Introduction

The problem of extended-target tracking (ETT) [1, 2] arises because of the sensor resolution capacities [3], the high density of targets, the sensor-to-target geometry, and so forth. For targets in near field of a high-resolution sensor, the sensor is able to receive more than one measurement (observation, or detection) at each time from different corner reflectors of a single target. In this case, the target is no longer known as a point object, which at most causes one detection at each time. It is called extended target. ETT is very valuable for many real applications [4, 5], such as ground or littoral surveillance, robotics, and autonomous weapons.The ETT problem has attracted great interest in recent years. Some approaches [6, 7] have been proposed for tracking a known and fixed number of the extended targets without clutter. Nevertheless, for the problem of tracking an unknown and varying number of the extended targets in clutter, most of the association-based approaches [8], such as nearest neighbor, joint probabilistic data association, and multiple hypothesis tracking, would no longer be applicable straightforwardly owing to their underlying assumption of point objects.Recently, the random-finite-set- (RFS-) based tracking approaches [9] have attracted extensive attention because of their lots of merits. The probability hypothesis density (PHD) [10] filter, developed by Mahler for tracking multiple point targets in clutter, has been shown to be computationally tractable alternative to full multitarget filter in the RFS framework. The sequential Monte Carlo (SMC) implementation for the PHD filter was devised by Vo et al. [11]. Then, Vo and Ma [12] devised the Gaussian mixture (GM) implementation for the PHD filter under the linear, Gaussian assumption on target dynamics, birth process, and sensor model. Actually the original intention of the PHD filter devised by Clark and Godsill is to address nonconventional tracking problems, that is, tracking in high target density, tracking closely spaced targets, and detecting targets of interest in a dense clutter background [13]. So it is especially suitable for the ETT problem.Given the Poisson likelihood model for the extended target [14], Mahler developed the theoretically rigorous PHD filter for the ETT problem in 2009 [15]. Under the linear, Gaussian assumption, the GM implementation for the extended-target PHD (EPHD) filter was proposed by Granström et al. [16], in 2010. Similar to the point-target GM-PHD filter, the GM-EPHD filter can also be extended to accommodate mildly nonlinear target dynamics using the extended Kalman (EK) filtering [17] approximation. The extension is called EK-GM-EPHD filter. Experimental results showed the EK-GM-EPHD filter was capable of tracking multiple humans, each of which gave rise to, on average, 10 measurements at each scan and was therefore treated as an extended target, using a SICK LMS laser range sensor [16].Although the GM-EPHD and EK-GM-EPHD filters have been successfully used for many real-world problems, there have been no results showing the convergence for the two filters. The convergence results on point-target particle-PHD and GM-PHD filters [18, 19] do not apply directly for the GM-EPHD and EK-GM-EPHD filters because of the significant difference between the measurement update steps of the PHD and EPHD filters. Therefore, to ensure the more successful and extensive applications of the EPHD filter to “real-life” problems, it is necessary to answer the following question: do the GM-EPHD and EK-GM-EPHD filters converge asymptotically toward the optimal filter and in what sense?The answer can actually be derived from Propositions3.2 and 3.3 in this paper. Proposition 3.2 demonstrates the uniform convergence [20–22] of the errors for the measurement update step of the GM-EPHD filter. In other words, given simple sufficient conditions, the approximation error of the measurement-updated EPHD by a sum of Gaussians is proved to converge to zero as the number of Gaussians in the mixture tends to infinity. In addition, the uniform convergence results for the measurement update step of the EK-GM-EPHD filter are derived from Proposition 3.3.


## 2. EPHD and GM-EPHD Filters

At timek, let xk be the state vector of a single extended target, and zk a single measurement vector received by sensor. Multiple extended-target states and sensor measurements can, respectively, be represented as finite sets Xk={xi,k}i=1nk and Zk={zi,k}i=1mk, where nk and mk denote the number of the extended targets and sensor measurements, respectively. A Poisson model is used to describe the likelihood function for the extended target according to Gilholm et al. [14]:
(2.1)lZk(xk)=e-γ(xk)∏zk∈Zkγ(xk)ϕzk(xk),
where ϕzk(xk) denotes the single-measurement single-target likelihood density; γ(xk) denotes the expected number of measurements arising from an extended target.The clutter is modeled as a Poisson RFS with the intensityκk(zk)=λkck(zk), where λk is the average clutter number per scan and ck(zk) is the density of clutter spatial distribution.Given the Poisson likelihood model for the extended targets, Mahler derived the EPHD filter using finite-set statistics [15, 23]. The prediction equations of the EPHD filter are identical to those of the point-target PHD filter [10]. The EPHD measurement update equations are
(2.2)υk(xk)=(1-pD,k(xk)+e-γ(xk)pD,k(xk)+∑℘k∠Zkω℘k∑Wk∈℘kηWk(xk)dWk)υk|k-1(xk),(2.3)ηWk(xk)=pD,k(xk)e-γ(xk)∏zk∈Wkγ(xk)ϕzk(xk)λkck(zk),(2.4)ω℘k=∏Wk∈℘kdWk∑℘k′∠Zk∏Wk′∈℘k′dWk′;dWk=δ|Wk|,1+〈υk∣k-1,ηWk〉,
where pD,k(xk) denotes the probability that the set of observations from the extended target will be detected at time k; ℘k∠Zk denotes that ℘k partitions set Zk [15], for example, let Z={z1,z2,z3}, then the partitions of Z are ℘1={{z1,z2,z3}}, ℘2={{z1},{z2},{z3}}, ℘3={{z1,z2},{z3}}, ℘4={{z1,z3},{z2}}, and ℘5={{z1},{z2,z3}}; |Wk| denotes the cardinality of the set Wk; δ|Wk|,1=1 if |Wk|=1, and δ|Wk|,1=0 otherwise; the notation 〈·,·〉 is the usual inner product. The measure in 〈·,·〉 of (2.4) is continuous, it defines the integral inner product
(2.5)〈υk∣k-1,ηWk〉=∫υk∣k-1(xk)ηWk(xk)dxk.By making the same six assumptions that are made in [12] and the additional assumption that γ(xk) can be approximated as functions of the mean of the individual Gaussian components, Granström et al. proposed the GM-EPHD filter [16]. At time k, let υk∣k-1Jk∣k-1 denote the GM approximation to the predicted EPHD υk∣k-1 with Jk∣k-1 Gaussian components, and υkJk the GM approximation to the measurement-updated EPHD υk with Jk Gaussian components. The prediction equations of the GM-EPHD filter are identical to those of point-target GM-PHD filter [12]. The GM-EPHD measurement update equations are as follows.Let the predicted EPHD be a GM of the form(2.6)υk∣k-1Jk∣k-1(xk)=∑i=1Jk|k-1wk|k-1(i)N(xk∣mk∣k-1(i),Pk∣k-1(i)),
where 𝒩(·|m,P) denotes the density of Gaussian distribution with the mean m and covariance P.Then, the measurement-updated EPHD is a GM given by(2.7)υkJk(xk)=υkND,Jk∣k-1(xk)+∑℘k∠Zk∑Wk∈℘kυkD,Jk∣k-1(xk,Wk),
where υkND,Jk|k-1(xk) denotes the Gaussian components handling no detections,
(2.8)υkND,Jk|k-1(xk)=∑j=1Jk|k-1wk(j)N(xk∣mk|k-1(j),Pk|k-1(j)),wk(j)=(1-(1-e-γ(mk∣k-1(j)))pD,k)wk∣k-1(j),mk(j)=mk∣k-1(j);Pk(j)=Pk∣k-1(j),
and υkD,Jk|k-1(xk,Wk) denotes the Gaussian components handling detected targets
(2.9)υkD,Jk∣k-1(xk,Wk)=∑j=1Jk∣k-1wk(j)N(xk∣mk(j),Pk(j)),(2.10)wk(j)=ω℘kJk∣k-1ηWk(mk∣k-1(j))dWkJk∣k-1wk∣k-1(j),(2.11)ω℘kJk∣k-1=∏Wk∈℘kdWkJk∣k-1∑℘k′∠Zk∏Wk′∈℘k′dWk′Jk∣k-1;dWkJk|k-1=δ|Wk|,1+〈υk∣k-1Jk∣k-1,ηWk〉,(2.12)ηWk(mk∣k-1(j))=pD,ke-γ(mk∣k-1(j))∏zk∈Wkγ(mk∣k-1(j))ϕzk(mk∣k-1(j))λkck(zk),(2.13)ϕzk(mk∣k-1(j))=N(zk∣Hkmk∣k-1(j),Rk+HkPk∣k-1(j)HkT),(2.14)Kk(j)=Pk∣k-1(j)H-kT(H-kPk∣k-1(j)H-kT+R-k)-1,(2.15)mk(j)=mk∣k-1(j)+Kk(j)([z1⋮z|Wk|]-H-kmk∣k-1(j));Pk(j)=(I-Kk(j)H-k)Pk∣k-1(j),(2.16)H-k=[Hk⋮Hk]}|Wk|;R-k=blkdiag(Rk,…,Rk⏞|Wk|),
where I denotes the identity matrix; pD,k has been assumed to be state independent; Hk and Rk denote the observation matrix and the observation noise covariance, respectively; blkdiag(·) denotes block diagonal matrix, the measure in 〈·,·〉 of (2.11) is discrete, and it defines the summation inner product
(2.17)〈υk∣k-1Jk∣k-1,ηWk〉=∑l=1Jk|k-1ηWk(mk∣k-1(l))wk∣k-1(l).


## 3. Convergence of the GM-EPHD and EK-GM-EPHD Filters

The convergence properties and corresponding proof of the initialization step, prediction step, and pruning and merging step for the GM-EPHD filter are identical to those for point-target GM-PHD filter [19]. The main difficulty and greatest challenge is to prove the convergence for the measurement update step of the filter.In order to derive the convergence results of the measurement update step for the GM-EPHD filter, the following lemma is first presented.Consider the following assumptions.B1
: After the prediction step at timek, υk∣k-1Jk∣k-1 converges uniformly to υk|k-1. In other words, for any given εk∣k-1>0  and any bounded measurable function φ∈B(ℝd), where B(ℝd) is the set of bounded Borel measurable functions on ℝd, there is a positive integer J such that
(3.1)|〈υk∣k-1Jk∣k-1-υk∣k-1,φ〉|≤εk∣k-1‖φ‖∞,
for Jk|k-1≥J, where ∥·∥∞ denotes ∞-norm. ∥φ∥∞≜sup(|φ|), sup(·)denotes the supremum.B2
: The clutter intensityκk(zk)=λkck(zk) is known a priori.B3
:γ(xk)∈Cb(ℝd), where Cb(ℝd) denotes the set of the continuous bounded functions on ℝd.Lemma 3.1.
Given a partition℘k={W1,k,W2,k,…,Wn,k} and suppose that assumptions B1–B3 hold, then
(3.2)|∏i=1,…,ndWi,kJk∣k-1-∏i=1,…,ndWi,k|≤εk∣k-1∑j=1,…,n‖ηWj,k‖∞∏i=1,…,n;i≠j(dWi,kJk∣k-1+dWi,k).The proof of Lemma3.1 can be found in Appendix A.The uniform convergence of the measurement-updated GM-EPHD is now established by Proposition3.2.Proposition 3.2.
After the measurement update step of the GM-EPHD filter, there exists a real numberak, dependent on the number of measurements such that
(3.3)|〈υkJk-υk,φ〉|≤akεk∣k-1‖φ‖∞,
where ak is defined by (B.10).The proof of the Proposition3.2 can be found in Appendix B.Proposition3.2 shows that the error for the GM-EPHD corrector converges uniformly to the true EPHD corrector at each stage of the algorithm and the corresponding error bound is also provided. The error tends to zero as the number of Gaussians in the mixture tends to infinity. However, from (B.10), it can be seen that the error bound for the GM-EPHD corrector depends on the number of all partitions of the measurement set. It is quickly realized that as the size of the measurement set increases, the number of possible partitions grows very large. Therefore, the number of Gaussians in the mixture to ensure the asymptotic convergence of the error to a given bound would grow very quickly with the increase of the measurement number.Now turn to the convergence for the EK-GM-EPHD filter, which is the nonlinear extension of the GM-EPHD filter. Due to the nonlinearity of the extended-target state and observation processes, the EPHD can no longer be represented as a GM. However, the EK-GM-EPHD filter can be adapted to accommodate models with mild nonlinearities. The convergence property and corresponding proof of the prediction step for the EK-GM-EPHD filter are identical to those for point-target EK-GM-PHD filter [19]. We now establish the conditions for uniform convergence of the measurement update step for the EK-GM-EPHD filter.Proposition 3.3.
Suppose that the predicted EK-EPHD is given by the sum of Gaussians(3.4)υk∣k-1EK,Jk∣k-1(xk)=∑i=1Jk∣k-1wk∣k-1(i)N(xk∣mk∣k-1(i),Pk∣k-1(i)),
and the ϕzk(xk) in (2.1) is given by the nonlinear single-measurement single-target equation zk=hk(xk,vk), where hk is known nonlinear functions and vk is zero-mean Gaussian measurement noise with covariance Rk, then the measurement-updated EK-EPHD approaches the Gaussian sum
(3.5)υk(xk)→υkEK,Jk(xk)=υkND,EK,Jk∣k-1(xk)+∑℘k∠Zk∑Wk∈℘kυkD,EK,Jk∣k-1(xk,Wk),
uniformly in xk and Zk as Pk|k-1(i)→0 for i=1,…,Jk∣k-1, and where
(3.6)υkND,EK,Jk∣k-1(xk)=∑i=1Jk∣k-1(1-pD,k+e-γ(mk∣k-1(i))pD,k)wk∣k-1(i)N(xk∣mk∣k-1(i),Pk∣k-1(i)),(3.7)υkD,EK,Jk∣k-1(xk,Wk)=∑i=1Jk∣k-1ω℘kEK,Jk∣k-1ηWkEK(mk∣k-1(i))dWkEK,Jk∣k-1wk∣k-1(i)N(xk∣mk(i),Pk(i)),(3.8)ω℘kEK,Jk∣k-1=∏Wk∈℘kdWkEK,Jk∣k-1∑℘k′∠Zk∏Wk′∈℘k′dWk′EK;dWkEK,Jk∣k-1=δ|Wk|,1+∑i=1Jk∣k-1wk∣k-1(i)ηWkEK(mk∣k-1(i)),(3.9)ηWkEK(mk∣k-1(i))=pD,ke-γ(mk∣k-1(i))×∏zk∈Wkγ(mk∣k-1(i))N(zk∣hk(mk∣k-1(i),0),Uk(i)Rk(Uk(i))T+Hk(i)Pk∣k-1(i)(Hk(i))T)λkck(zk),(3.10)Hk(i)=∂hk(xk,0)∂xk|xk=mk∣k-1(i);Uk(i)=∂hk(mk∣k-1(i)n,vk)∂vk|vk=0,(3.11)Kk(i)=Pk∣k-1(i)(H-k(i))T(H-k(i)Pk∣k-1(i)(H-k(i))T+U-k(i)Rk(U-k(i))T)-1,(3.12)mk(i)=mk∣k-1(i)+Kk(i)([z1⋮z|Wk|]-[h(mk∣k-1(i),0)⋮h(mk∣k-1(i),0)]);Pk(i)=(I-Kk(i)H-k(i))Pk∣k-1(i),(3.13)H-k(i)=[Hk(i)⋮Hk(i)]}|Wk|;U-k(i)=[Uk(i)⋮Uk(i)]}|Wk|,The proof of Proposition3.3 can be found in Appendix C.From Propositions3.2 and 3.3, we can obtain that the EK-GM-EPHD corrector uniformly converges to the true EPHD corrector in xk and Zk under the assumptions that Pk|k-1(i)→0 for i=1,…,Jk∣k-1 and the number of Gaussians in the mixture tends to infinity. These assumptions may be too restrictive or be unrealistic for practical problems, although the EK-GM-EPHD filter have demonstrated its potential for real-world applications. However, Propositions 3.2 and 3.3 give further theoretical justification for the use of the GM-EPHD and EK-GM-EPHD filters in ETT problem.


## 4. Simulations

Here we briefly describe the application of the convergence results for the GM-EPHD and EK-GM-EPHD filters to the linear and nonlinear ETT examples.Example 4.1 (GM-EPHD filter to linear ETT problem).
Consider a two-dimensional scenario with an unknown and time varying number of the extended targets observed over the region[-1000,1000]×[-1000,1000] (in m) for a period of T=45 time steps. The sampling interval is Δt=1s. At time k, the actual number of the existing extended targets is nk and the state of the ith target is xi,k=[xi,k,yi,k,x˙i,k,y˙i,k,x¨i,k,y¨i,k]T (i=1,…,nk). Assume that the process noise ϖi,k of the ith extended target is independent and identically distributed (IID) zero-mean Gaussian white noise with the covariance matrix Qi,k. Then the Markovian transition density of xi,k could be modeled as
(4.1)fk|k-1(xi,k∣xi,k-1)=N(xi,k∣Φi,kxi,k-1,Qi,k),
where Φi,k is discrete-time evolution matrix. Here Φi,k and Qi,k are given by the constant acceleration model [24], as
(4.2)Φi,k=[1ΔtΔt221Δt1]⊗I2;Qi,k=σϖ2[Δt44Δt32Δt22Δt32Δt22ΔtΔt22Δt1]⊗I2;I2=[11],
where “⊗” denotes the Kronecker product. The parameter σϖ is the instantaneous standard deviation of the acceleration, given by σϖ=0.05m/s2.
Note that the objective of this paper is to focus on the convergence analysis for the GM-EPHD and EK-GM-EPHD filters, rather than the simulation of the extended-target motions. Therefore, although the proposed evolutions for the extended targets seem to be uncritical and oversimplifying, they will have little effect on the intention of the paper. Readers could be referred to [25] for further discussion on the extended-target motion models. The models proposed in [25] can also be accommodated within the EPHD filter straightforwardly.
At timek, the x-coordinate and y-coordinate measurements of the extended targets are generated by a sensor located at [0,0]T. The measurement noise vk is IID zero-mean Gaussian white noise with covariance matrix Rk=diag(σx2,σy2), where diag(·) denotes the diagonal matrix, σx and σy are, respectively, standard deviations of the x-coordinate and y-coordinate measurements. In this simulation, they are given as σx=σy=25m. The single-measurement single-target likelihood density ϕzk(xi,k) is
(4.3)ϕzk(xi,k)=N(zk∣Hkxi,k,Rk),
where
(4.4)Hk=[100000010000].
The detection probability of the sensor ispD,k(xk)=0.95.
In this simulation, it is assumed that the effect of the shape for each extended target is much smaller than that of the measurement noise. Hence, the shape estimation is not considered here.
At timek, the number of the measurements arising from the ith extended target satisfies Poisson distribution with the mean γ(xi,k). In this simulation, it is given as γ(xi,k)=3 (i=1,…,nk).
The clutter is modeled as a Poisson RFS with the intensityκk(zk)=λkck(zk). In this example, the actual clutter density is ck(zk)=𝒰(zk). It means that the clutter is uniformly distributed over the observation region.
Figure1 shows the true trajectories for extended targets and sensor location.Figure 1
The true trajectories for extended targets and sensor location.In Figure1, “Δ” denotes the sensor location, “◯” denotes the locations at which the extended targets are born, “□” denotes the locations at which the extended targets die, and “+” denotes the measurements generated by the extended targets. Extended target 1 is born at 1 s and dies at 25 s. Extended target 2 is born at 1 s and dies at 30 s. Extended target 3 is born at 10 s and dies at 35 s. Extended target 4 is born at 20s and dies at 45 s.The intensity of the extended-target birth at timek is modeled as
(4.5)βk(xk)=λβfβ(xk∣ψβ),
where λβ is the average number of the extended-target birth per scan, fβ(xk|ψβ) is the probability density of the new born extended-target state, and ψβ is the set of the density parameters. In this example, they are taken as λβ=0.05, fβ(xk|ψβ)=πβ1𝒩(xk|μβ1,Σβ1)+πβ2𝒩(xk|μβ2,Σβ2), where ψβ={πβ1,πβ2,μβ1,μβ2,Σβ1,Σβ2}, πβ1=πβ2=0.5, μβ1=[-600,750,0,0,0,0]T, μβ2=[-650,-800,0,0,0,0]T, and Σβ1=Σβ2=diag(400,400,100,100,9,9).The GM-EPHD filter is used to estimate the number and states of the extended targets in the linear ETT problem. We now conduct Monte Carlo (MC) simulation experiments on the same clutter intensity and target trajectories but with independently generated clutter and target-generated measurements in each trial. Via comparing the tracking performance of the GM-EPHD filter in the various numberJk of Gaussians in the mixture and in various clutter rate λk, the convergence results for the algorithm can be verified to a great extent. For convenience, we assume Jk=J and λk=λ at each time step. Assumptions B2–B3 are satisfied in this example. So, the GM-EPHD filter uniformly converges to the ground truth.The standard deviation of the estimated cardinality distribution and the optimal subpattern assignment (OSPA) multitarget miss distance [26] of order p=2 with cutoff c=100m, which jointly captures differences in cardinality and individual elements between two finite sets, are used to evaluate the performance of the method. Given the clutter rate λ=50, Table 1 shows the time averaged standard deviation of the estimated cardinality distribution and the time averaged OSPA from the GM-EPHD filter in various J via 200 MC simulation experiments.Table 1
Time averaged standard deviation of the estimated cardinality distribution and time averaged OSPA (m) from the GM-EPHD filter in variousJ given λ=50.
Gaussian numberJ in the mixture
50
100
300
500
700
Time averaged standard deviation of the estimated cardinality distribution from the GM-EPHD filter
2.12
1.39
0.97
0.71
0.58
OSPA (m) from the GM-EPHD filter
83.5
58.7
49.6
43.1
39.5Table1 shows that both the standard deviation of the estimated cardinality distribution and OSPA decrease with the increase of the Gaussian number J in the mixture. This phenomenon can be reasonably explained by the convergence results derived in this paper. First, according to Proposition 3.2, the error of the GM-EPHD decreases as J increases; then, the more precise estimates of the multitarget number and states can be derived from the more precise GM-EPHD, which eventually leads to the results presented in Table 1.GivenJ=700, Table 2 shows the time averaged standard deviation of the estimated cardinality distribution and the time averaged OSPA from the GM-EPHD filter in various clutter rate λ via 200 MC simulation experiments. Obviously, the number of the measurements collected at each time step increases with the increase of λ.Table 2
Time averaged standard deviation of the estimated cardinality distribution and time averaged OSPA (m) from the GM-EPHD filter in variousλ given J=700.
Clutter rateλ
50
100
200
300
400
Time averaged standard deviation of the estimated cardinality distribution from the GM-EPHD filter
0.58
0.70
0.95
1.23
1.48
OSPA (m) from the GM-EPHD filter
39.5
42.9
49.0
56.1
61.7From Table2, it can be seen that the errors of the multitarget number and state estimates from the GM-EPHD filter grow significantly with the increase of λ. A reasonable explanation for this is that the partition operation included in (B.10) leads that the error bound of the GM-EPHD corrector grows very quickly with the increase of the measurement number. Therefore, Table 2 consists with the convergence results established by Proposition 3.2, too.Example 4.2 (EK-GM-EPHD filter to nonlinear ETT problem).
The experiment settings are the same as those of Example4.1 except the single-measurement single-target likelihood density ϕzk(xi,k). The range rk and bearing θk measurements of the extended targets are generated with the noise covariance matrix Rk=diag(σr2,σθ2), where σr and σθ are, respectively, standard deviations of the range and bearing measurements. In this simulation, they are given as σr=25m and σθ=0.025rad. The ϕzk(xi,k) becomes
(4.6)ϕzk(xi,k)=N(zk∣hk(xi,k),Rk),
where
(4.7)hk(xi,k)=[xi,k2+yi,k2arctanyi,kxi,k]T.
The EK-GM-EPHD filter is used to estimate the number and states of the extended targets in the nonlinear ETT problem. Givenλ=50, Table 3 shows the time averaged standard deviation of the estimated cardinality distribution and the time averaged OSPA from the EK-GM-EPHD filter in various J via 200 MC simulation experiments while, given J=700, Table 4 shows the time averaged standard deviation of the estimated cardinality distribution and the time averaged OSPA from the EK-GM-EPHD filter in various λ via 200 MC simulation experiments.Table 3
Time averaged standard deviation of the estimated cardinality distribution and time averaged OSPA (m) from the EK-GM-EPHD filter in variousJ given λ=50.
Gaussian numberJ  in the mixture
50
100
300
500
700
Time averaged standard deviation of the estimated cardinality distribution from the EK-GM-EPHD filter
3.15
2.29
1.77
1.21
0.76
OSPA (m) from the EK-GM-EPHD filter
93.2
86.7
75.3
54.6
43.9Table 4
Time averaged standard deviation of the estimated cardinality distribution and time averaged OSPA (m) from the EK-GM-EPHD filter in variousλ given J=700.
Clutter rateλ
50
100
200
300
400
Time averaged standard deviation of the estimated cardinality distribution from the EK-GM-EPHD filter
0.76
0.92
1.29
1.61
1.92
OSPA (m) from the EK-GM-EPHD filter
43.9
48.1
55.8
67.8
79.5As expected, Tables3 and 4, respectively, show that the errors of the multitarget number and state estimates from the EK-GM-EPHD filter decrease with the increase of J and increase with the increase of λ. These consist with the convergence results established by Propositions 3.2 and 3.3. In addition, comparing Tables 1 and 2 with Tables 3 and 4, it can be seen that the errors from the EK-GM-EPHD filter are obviously larger than the errors from the GM-EPHD filter given the same J and λ. The additional errors from the EK-GM-EPHD filter are caused by the reason that the condition Pk|k-1(i)→0 for i=1,…,Jk|k-1 in Proposition 3.3 is very difficult to approach in this example.


## 5. Conclusions and Future Work

This paper shows that the recently proposed GM-EPHD filter converges uniformly to the true EPHD filter as the number of Gaussians in the mixture tends to infinity. Proofs of uniform convergence are also derived for the EK-GM-EPHD filter. Since the GM-EPHD corrector equations involve with the partition operation that grows very quickly with the increase of the measurement number, the future work is focused on studying the computationally tractable approximation for it and providing the convergence results and error bounds for the approximate GM-EPHD corrector.



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*Source: 141727-2012-08-07.xml*