Open access peer-reviewed chapter
By Javier Prieto, Santiago Mazuelas, Alfonso Bahillo, Patricia Fernández, Rubén M. Lorenzo and Evaristo J. Abril
Submitted: April 24th 2012Reviewed: November 27th 2012Published: February 13th 2013
DOI: 10.5772/55263
Downloaded: 1391
With the arrival of global navigation satellite systems (GNSS), in-car navigation has increasingly become an essential tool for the automotive industry. However, the performance of GNSS is compromised in harsh environments where there is not a line of sight (LOS) to satellites, e.g., tunnels, covered parking areas and dense urban canyons [1]. Hence, in-car navigation requires a localization technology that operates with robustness in such circumstances. The development of vehicular ad-hoc networks (VANETs) provides a promising platform to fulfill this requirement [2].
In VANETs, an on-board unit (OBU) inside the vehicle communicates with other OBUs or with stationary roadside units (RSUs), in vehicle-to-vehicle (V2V) and vehicle-to-infrastructure (V2I) communications, respectively [3]. Cooperation between OBUs can provide good position estimates in V2V communication [4-5]. However, the quick topology changes required by V2V approaches make V2I communication be the preferred option for in-car navigation in harsh environments [6]. In V2I communication, the position of an OBU (the target) can be estimated from range-related measurements taken on the radio-frequency signals transmitted to and from the RSUs (the anchors) [7]. However, the changeable and unpredictable characteristics of the wireless channel in harsh environments make multipath and non-line of sight (NLOS) propagation conditions be predominant [8-9]. Therefore, conventional positioning systems designed for tractable and static signal behavior cannot guarantee an adequate performance.
The position information extracted from the radio-frequency signals varies according to the type of measurement taken. Techniques based on time of arrival (TOA) [9-10] or received signal strength (RSS) [11-12] measurements obtain range-related information, whereas techniques based on angle of arrival (AOA) or time difference of arrival (TDOA) measurements extract information related to directions or difference of distances, respectively [13-14]. AOA and TDOA measurements entail significant costs of antenna-array integration or synchronizing devices. In this chapter, we focus on RSS and TOA measurements that can provide accurate localization with an appropriate complexity.[1] -
Range or position estimation is an inference problem where the observations are the RSS and TOA measurements [15-16]. From a Bayesian perspective, determining the posterior distribution of ranges or positions from observations is the optimal approach [17-25]. Then, ranges or positions can be obtained by means of the maximum a posteriori (MAP) or the minimum mean square error (MMSE) estimators.
The optimality of the above mentioned methods depends on the fit between the model assumed for the relationship between measurements and ranges or positions (i.e., the likelihood function) and the actual behavior of the measurements. Tractable and static models for the likelihoods based on Gaussian distributions accurately explain the behavior of measurements only in open areas [26-28]. For harsh environments, several techniques have been developed to address the complex behavior of wireless signal metrics. In the TOA case, the NLOS bias causes range overestimation. Thus, a common procedure is to detect and remove NLOS measurements [29]; other techniques utilize prior knowledge about this NLOS error to subtract it and adjust the measurements to their LOS values [27,30]. In the RSS case, the performance depends on the estimation of the parameters that characterize the propagation channel at each time [12,26]. Certain approaches deal with the dynamic nature of RSS metric through fingerprinting or machine learning [11,21,31]; however, their accuracy is sensitive to fast environmental changes and they do not fuse different signal metrics.
Range and position estimation can be improved by exploiting the relationship among positions in time through Bayesian filtering. Kalman filtering techniques rely on Gaussian models that are not adequate for harsh environments. Different alternative methods based on variations of such filters, as well as on particle filters (PFs), have been proposed: low complexity non-linear/non-parametric adaptive modeling is used for filtering of RSS fingerprints in [11,21]; recursive Bayesian estimation together with multipath and NLOS propagation effects are considered in [22-23]; TOA and RSS data fusion is performed in [32-34]; hybrid information is exploited by particle filtering in [24]; and RSS/TOA Bayesian fusion for multipath and NLOS mitigation are performed in [25]. However, these methods require prior information achieved by arduous training phases or rely on assumptions non-realistic for harsh environments, such as Gaussian and static models.
This chapter presents a framework for adaptive data fusion to handle the difficulties described above, based on non-parametric dynamic modeling of the likelihood. The subsequent usage of a PF leads to the adaptive likelihood particle (ALPA) filter. As we show, the estimation can be carried out without requiring any calibration stage, thus enabling localization capabilities to pre-existing wireless infrastructures, such as VANETs based on V2I communication. The main contributions of this chapter are as follows:
We present techniques for adaptive and systematic modeling of the relationship between measurements and positions, by means of a dynamic and empirical likelihood function.
We present a model for Bayesian fusion of TOA and RSS measurements, based on nonlinear and non-Gaussian Bayesian filtering and the likelihoods derived over time.
We show the suitability of the proposed techniques by experimentation performed using common wireless local area network (WLAN) devices.
We show the near-optimality of the method by comparing its performance to the posterior Cramér-Rao lower bound (CRLB).
Both empirical and simulation results show that the proposed methods significantly improve the accuracy of conventional approaches with an important reduction on the number of measurements needed.
The structure of the rest of this chapter is as follows: Section II defines the position estimation problem; Section III addresses this problem under a hidden Markov model (HMM) and defines the dynamic and measurements models; Section IV presents the adaptive data fusion technique for likelihood modeling and the recursive Bayesian approach for solving the resulting non-linear and non-Gaussian problem; Section V shows the experimental and simulation results; Section VI includes a discussion on complexity; and finally, Section VII draws the conclusions.
Notations: The notation
In the following, we consider a two-dimensional scenario where a mobile target (e.g., a car equipped with an OBU) moves freely. To determine its position, the target communicates with several anchors (the RSUs) with known positions. Since the localization system can get measurements in discrete times
Next section establishes the probabilistic relationship between vectors
In addition to the information conveyed by the measurements, the fact that the sequence
where
The correlation in time expressed in (1) implies that
Hidden Markov Model for positional-states and measurements evolution. The relationship between yk and yk-1 and the relationship between zk and yk are the only two kinds of dependence.
The conditional independence assumptions reflected in Figure 1 lead to two kinds of dependence between the random variables [36],
Dynamic model: establishes the relationship between the state vector in time
Measurements model: establishes the relationship between the measurements and the state vector in each time, i.e.,
Then, the joint distribution of all the random variables involved in the process is given by,[1] -
The modeling as an HMM shown in (2) makes possible to infer the posterior distribution
The dynamic model of the positional-state vector can be obtained from the evolution in time given by (1), and by approximating each
where
is the transition matrix, and
where
The second ingredient to characterize the HMM is the measurements model or likelihood,
In a given specific instant and place, the RSS values are affected by the distance between emitter and receiver. The attenuation caused by the distance between two nodes is known as path-loss and is proportional to this distance raised to a certain exponent, called path-loss exponent [7,12,15,26]. However, the RSS values are likewise affected by a wide range of unpredictable factors, such as multipath propagation (fast fading) and shadowing (slow fading) [37]. By reflecting these factors in the Friis transmission equation for free-space, the relationship between the received signal strength,
where
By following the procedure described in [26] and taking logarithmic units, we obtain the measurements model for RSS values,
where
The distance between emitter and receiver also affects the time taken by the signal to be propagated from one node to the other. By assuming known the signal speed, we can infer this distance by means of a linear transformation of the TOA values. Due to the technical difficulty of synchronizing devices in a wireless network, techniques that use round-trip time estimation are the most attractive to estimate delays [10,28]. In this case, the processing time at the device that has to transmit the echo causes the relationship between TOA and distance to be affine linear (it has an intercept term). Then, we can model the relationship between the delay,
where
From the above discussion, we can notice that in all cases the expected value of the measurements is
the relationship between measurements related to distances and distances is nonlinear and non-Gaussian;
such relationship highly depends on the propagation environment that can change rapidly.
These two factors render the linear-Gaussian assumption inadequate for the measurements model,
Conventional non-Bayesian approaches for parameter estimation are based on maximum-likelihood (ML) estimation (in our case the maximization of
In the above mentioned context, the task is to determine the posterior distribution of positional-states given the measurements,
In the case of modeling the positional-state and measurements evolution as an HMM, the expression (2) provides a way to determine the posterior distribution iteratively,
and for
From the posterior distribution,
leading to a process called filtering.[1] - By replacing (9) in (10) we obtain,
By assuming known the posterior distribution at
Prediction: from the dynamic model we obtain the prediction of the positional-state in time
Update: from the measurements model we correct the prediction when a new set of measurements,
and the normalization constant,
Hence, the objective is to infer the hidden positional-state vector in each time,
In order to perform the described filtering process, we need the likelihood function of the measurements
Density functions involved in filtering process for range and position estimation (darker zones have higher probability): (a) the target with the OBU moves in tk with respect to its position in tk-1; (b) the posterior density in tk-1 is known; (c) from the dynamic model we perform the prediction; (d) in tk the target receives a new set of measurements; (e) from the likelihood we update the prediction to obtain the posterior density in tk.
The sets of RSS and TOA measurements obtained in each instant consist of samples from the random variable
where
By assuming that the distribution of the measurements
Proposition 1. Let
where the expectation
Proof: see [48].
The Proposition 1 enables to obtain individual likelihoods from a set of measurements. Data fusion from different signal metrics (i.e., RSS and TOA) is carried out by combining these likelihoods. Let
where the likelihood of each kind of measurement can be dynamically obtained from (17).
In order to describe how the presented adaptive data fusion operates, Figures 3-4 show the histogram of 100 RSS and 100 TOA measurements taken at a fixed distance with the measuring systems described in [12] and [10], respectively. These figures also represent the corresponding Gaussian pdf and the adaptive pdf obtained by means of the kernel-based expression given by (15) and (16).[1] - From those figures, we can point out that, despite the fact that the true density is unknown, the presented adaptive pdf can express the dynamic behavior of RSS/TOA measurements in harsh environments with better accuracy than histogram and Gaussian density estimates [49-50].
The adaptive density accurately approximates the complex randomness of RSS measurements in harsh environments.
The adaptive density accurately approximates the complex randomness of TOA measurements in harsh environments.
In Figure 5 we illustrate the RSS/TOA data fusion process by representing the adaptive likelihood function obtained by means of expressions (17) and (18).[1] -
The adaptive RSS/TOA data fusion, defined by Proposition 1 and (18), results, in this case, in an improvement of 0.5 meters in ML estimator compared with the Gaussian case, which is equivalent to a reduction of 18% of the error.
From Figure 5, we can point out that the adaptive likelihood function provides more information about the distance than the Gaussian model, by combining the individual adaptive likelihoods obtained with RSS and TOA measurements. Moreover, the height of both functions reflects the more reliable information obtained by adaptive estimation. From that figure, we also observe the improvement achieved by means of data fusion with respect to the individual estimates. This likelihood function leads to the ALPA filter defined in the following section.
Within the framework provided by the HMM, if both dynamic and measurements models are linear-Gaussian, all the posterior distributions are also Gaussian. In this case, all the involved density functions are completely described by their mean vectors and covariance matrices, obtained by a KF [19]. In the case of interest in this chapter, the models in the HMM are neither linear nor Gaussian, and then, the usage of KFs is suboptimal. In order to circumvent this drawback, the classical solution consists of using extended KFs (EKF) [23,25]. However, better performances can be obtained by PFs that let the usage of more general and flexible models [17,19] as the adaptive likelihood described in the previous section.
A PF represents the posterior distribution through a discrete distribution, where the support points and their probabilities are called particles and weights, respectively. To estimate the posterior distribution, we need to iteratively obtain a certain number of samples (particles) and probabilities (weights) capable of representing the posterior distribution. These particles and weights can be obtained by a method known as sequential-importance-sampling (SIS) [19,51], where the weight of the different particles can be determined by evaluating the likelihood function pointwise. Therefore, more realistic models such as the presented adaptive likelihood function for data fusion can be used, leading to the ALPA filtering algorithm describe in Table 1.
| i. Initialization: ∙ Initial particles: draw ∙ Initial weights: ii. Recursive estimation: for ∙ Particles in instant ∙ From RSS measurements and Proposition 1, evaluate the weight of each particle. For | |
| ∙ From TOA measurements and Proposition 1, evaluate the weight of each particle. For | |
| ∙ Evaluate for | |
| ∙ Normalization: for | |
ALPA filtering.
To implement the algorithm detailed in Table 1, we have to choose a proposal distribution, where the most popular choice is to use the transition prior given by the dynamic model, i.e.,
Therefore, in order to use this algorithm, we have to obtain samples from the transition prior and evaluate the adaptive likelihood function pointwise. Figure 6 summarizes how this filter works with the proposal distribution chosen. First, we generate particles from the proposal distribution, in this case, the prior distribution,
Transition prior and likelihood functions. Particles are obtained by sampling from the prior and weighting from the likelihood.
In this SIS algorithm, as
where a small
The goal of this section is to quantify the performance of the methods presented in the above sections, leading to the ALPA filter. In order to do that, we obtained experimental data in a real indoor scenario by using the systems described in [10] and [12], and we ran numerous Monte Carlo simulations. In the following, we compare the performance of the introduced techniques with conventional approaches as well as with the CRLB.
We use the dynamic and measurements models above described together with the following state vector and prior information, depending on whether we estimate ranges or positions,
Range estimation: we use a state vector
Position estimation: we use a state vector
For the experimental data, the target carried a laptop equipped with an IEEE 802.11b/g adapter and the measuring systems described in [10] and [12]. The anchors consisted of IEEE 802.11b/g access points (APs). In the RSS case, the anchors periodically sent beacon frames (at a frequency of
As mentioned above, in a realistic scenario, NLOS propagation together with multipath effects constitute the major drawback of localization in harsh environments. This section illustrates the behavior of the proposed algorithm during a typical path followed by a mobile target in an indoor scenario. We carried out a measurement campaign inside an office building cluttered with clusters of objects and people moving freely in the area of the measurements. The propagation conditions were even harsher than the ones commonly find by an OBU placed within a car. Figure 8 shows the trajectory of 65 meters as well as the position of the 4 APs. It took 100 seconds to complete the whole trajectory, receiving a new set of measurements every second (
In Table 2, we compare the error achieved with the proposed ALPA range estimation method in the presented scenario to the error obtained with conventional approaches [15,24]. We specify the results for RSS-only and TOA-only cases, and for their fusion. Specifically, we call,
ML-RSS, ML-TOA, ML-Fusion: the range estimates obtained by means of the ML estimator. We utilize as likelihood function the convolution of the likelihood reported by the measurements (log-normal in the RSS case and Gaussian in the TOA case) and a Gaussian distribution corresponding to the bias.[1] - The likelihood for the fusion is computed from (18).
AML-RSS, AML-TOA, AML-Fusion: the ranges that correspond to the result of obtaining the maximum of the adaptive likelihood computed by means of Proposition 1, and (18) in the fusion case.
EKF-RSS, KF-TOA, EKF-Fusion: the result of applying EKF and KF filters for RSS and TOA measurements, respectively, using the same bias distributions as in the ML case, and the dynamic model given by (3).
ALPA-RSS, ALPA-TOA, ALPA-Fusion: the range estimates obtained by the ALPA filtering described in Table 1, where
We summarize for all these methods the quartiles of the absolute error in range estimates as well as the root mean squared error (RMSE), which incorporates both systematic (bias) and random errors. In order to study the influence of the number of measurements,
Figure 7 depicts the pdf of the absolute error in range estimation after applying AML-Fusion and ALPA-Fusion methods, taking
| Quartiles | RMSE | Quartiles | RMSE | Quartiles | RMSE | Quartiles | RMSE | |
| ML-RSS | 1.64-3.12-5.45 | 7.01 | 1.28-2.94-4.96 | 5.32 | 1.36-2.72-4.68 | 4.34 | 1.27-2.74-4.74 | 4.58 |
| ML-TOA | 2.09-3.92-7.68 | 6.42 | 1.55-3.40-5.64 | 5.00 | 1.26-2.69-4.40 | 3.87 | 1.12-2.44-4.00 | 3.55 |
| ML-Fusion | 1.52-3.16-5.87 | 5.25 | 1.26-2.66-4.73 | 4.23 | 1.09-2.24-3.89 | 3.55 | 0.87-2.18-3.61 | 3.26 |
| AML-RSS | 1.69-3.25-5.27 | 5.64 | 1.44-2.92-5.06 | 4.71 | 1.32-2.74-4.64 | 4.27 | 1.31-2.70-4.50 | 4.20 |
| AML-TOA | 2.06-3.74-7.38 | 6.28 | 1.52-3.31-5.57 | 4.93 | 1.18-2.61-4.27 | 3.81 | 1.03-2.38-3.86 | 3.48 |
| AML-Fusion | 1.38-2.91-5.19 | 4.49 | 1.15-2.32-3.65 | 3.49 | 0.86-1.91-3.39 | 3.06 | 0.83-1.83-3.26 | 2.91 |
| EKF-RSS | 0.84-2.22-4.26 | 3.82 | 1.06-2.59-4.21 | 3.81 | 1.21-2.43-4.07 | 3.76 | 1.17-2.55-4.04 | 3.69 |
| KF-TOA | 1.11-2.37-3.95 | 3.60 | 1.10-2.06-3.63 | 3.04 | 0.81-1.76-2.97 | 2.53 | 0.86-1.63-2.95 | 2.36 |
| EKF-Fusion | 0.93-1.90-3.24 | 2.78 | 0.86-1.82-3.15 | 2.59 | 0.82-1.62-2.62 | 2.25 | 0.74-1.49-2.55 | 2.10 |
| ALPA-RSS | 0.82-2.33-4.63 | 3.88 | 1.17-2.58-4.30 | 3.79 | 1.20-2.48-4.18 | 3.75 | 1.21-2.64-4.17 | 3.78 |
| ALPA-TOA | 0.94-2.04-3.33 | 3.11 | 0.95-1.90-3.06 | 2.69 | 0.72-1.48-2.63 | 2.52 | 0.76-1.50-2.64 | 2.32 |
| ALPA-Fusion | 0.84-1.72-2.95 | 2.58 | 0.80-1.70-2.85 | 2.35 | 0.69-1.37-2.36 | 2.22 | 0.70-1.45-2.40 | 2.08 |
Range estimation error quartiles and RMSE obtained with different algorithms as a function of the number of measurements. All error values are in meters.
Analogously, in Figures 8-9 and Table 3, we summarize the results in position estimation. In this case, we call,[1] -
ML-RSS, ML-TOA, ML-Fusion: the positions obtained with the ML distances and a trilateration technique based on the radical axis of the circles drawn at each anchor’s position [10,12-13].
EKF-RSS, EKF-TOA, EKF-Fusion: the positions obtained by means of an EKF whose measurements model relates the measurements to the target’s position.
PF-RSS, PF-TOA, PF-Fusion: the result of applying the ALPA filter described in Table 1 to the positional-states, with
The height and width of the pdf corresponding to the error achieved by the ALPA filter reflect its better performance in comparison to other conventional range estimation techniques. 10 RSS and 10 TOA measurements were taken with respect to each anchor.
| Quartiles | RMSE | Quartiles | RMSE | Quartiles | RMSE | Quartiles | RMSE | |
| ML-RSS | 3.83-5.91-8.49 | 12.99 | 3.32-5.21-7.49 | 8.91 | 3.35-4.94-6.98 | 6.64 | 3.26-5.00-6.60 | 7.43 |
| ML-TOA | 3.95-6.14-8.03 | 7.64 | 2.80-4.05-6.64 | 5.70 | 2.24-3.34-5.16 | 4.57 | 1.63-3.20-4.71 | 4.09 |
| ML-Fusion | 3.15-4.95-7.04 | 6.73 | 2.40-3.71-6.11 | 5.10 | 1.93-3.03-4.93 | 4.34 | 1.64-3.03-4.53 | 3.89 |
| EKF-RSS | 2.94-4.46-6.18 | 5.11 | 3.47-4.83-6.85 | 5.83 | 3.02-4.12-6.33 | 5.24 | 3.02-4.24-6.40 | 5.24 |
| KF-TOA | 1.77-2.79-4.25 | 3.54 | 2.05-2.80-3.64 | 3.11 | 1.54-2.28-3.09 | 2.61 | 1.50-2.22-3.14 | 2.51 |
| EKF-Fusion | 2.20-3.24-4.30 | 3.50 | 2.08-2.99-3.90 | 3.25 | 1.76-2.32-3.00 | 2.57 | 1.71-2.13-2.98 | 2.41 |
| ALPA-RSS | 1.93-3.28-5.18 | 4.36 | 3.16-3.91-5.18 | 4.68 | 2.38-3.09-4.61 | 4.23 | 2.72-3.65-4.97 | 4.37 |
| ALPA-TOA | 1.90-2.59-3.76 | 3.37 | 1.63-2.54-3.63 | 2.98 | 1.08-1.98-3.25 | 2.66 | 1.35-2.18-3.05 | 2.63 |
| ALPA-Fusion | 1.77-2.86-3.46 | 3.14 | 1.92-2.61-3.34 | 2.82 | 1.23-1.85-3.15 | 2.49 | 1.28-2.00-2.64 | 2.40 |
Position estimation error quartiles and RMSE obtained with several algorithms as a function of the number of measurements. All error values are in meters.
Trajectory followed by the target and position estimates for different positioning methods. 10 RSS and 10 TOA measurements were taken with respect to each anchor.
Figure 9 depicts the pdf of the error in position estimation for the three mentioned RSS/TOA fusion algorithms, taking
The proposed ALPA filter obtains the best performance with an error lower than 3 meters for more than 63% of the positions.
Figures 8-9 and Table 3 show the better performance of the proposed ALPA filter for all the analyzed scenarios, resulting, for example, in an RMSE of 2.82 meters for the case of only using
The CRLB provides a lower bound on the minimum achievable mean squared estimation error for any unbiased estimator. In what follows, we use such metric to assess the optimality of the presented ALPA filter against such lower bound.
The Bayesian version of the CRLB is known as the Van Tress CRLB [53], or posterior CRLB, since it is obtained from the posterior distributions of the random state vector [54]. In our case, for each time instant
where
Tichavský et al. proposed a recursive formula to compute the FIM [55]. For the particular case of the linear-Gaussian dynamic model in (3), being
and
To start this recursion, we assume the initial density as Gaussian, then, the initial FIM coincides with its covariance matrix.
Figure 10 compares the RMSE obtained in range estimation by means of the proposed ALPA-Fusion filter with the RMSE obtained by applying the EKF-Fusion method, and with the square root of the CRLB.[1] - To obtain such curves, we simulated a trajectory of 85 positions and carried out
The near-optimal performance of the proposed ALPA filter in harsh environments is corroborated by comparison with the CRLB.
The key issue in PFs is the exponential growth of computational complexity as a function of the dimension of the state vector,
Moreover, from Proposition 1, the complexity of the likelihood grows exponentially with the number of samples. However, this complexity can be reduced by removing redundant components from the RSS and TOA pdfs or from the resulting fusion mixture. To this aim, different criteria such as William‘s criterion [58], Kullback-Leibler distance [59] or clustering [60] can be utilized. Therefore, considering the improvement achieved in range and position estimation with
In this chapter we have presented an adaptive likelihood function for robust data fusion in localization systems. Based on this likelihood, we have developed the ALPA filter for range and position estimation. This ALPA filter presents several advantages over conventional techniques,
it does not assume any parametric statistical model, utilizing the empirical distribution of the measurements at each time by means of Gaussian kernels;
it adaptively fuses RSS and TOA data being extensible to any other type of measurement;
it takes advantage of the relationship among positions in time by using Bayesian filtering;
it addresses the non-linear and non-Gaussian behavior of the measurements by using particle filtering.
These advantages result in a noticeable improvement with respect to other conventional techniques, as corroborated by the experimental and simulation results. Under NLOS and multipath conditions, ALPA filter obtains not only an RMSE in position estimation lower than 3 meters with only 10 RSS and 10 TOA measurements, but also an error remarkably close to the theoretical benchmark provided by the CRLB.
Therefore, ALPA filter is a valuable choice to provide localization in V2I communication systems. Its extension to cooperative localization would make this localization also possible in VANETs based on V2V communication.
© 2013 The Author(s). Licensee IntechOpen. This chapter is distributed under the terms of the Creative Commons Attribution 3.0 License, which permits unrestricted use, distribution, and reproduction in any medium, provided the original work is properly cited.
1391total chapter downloads
8Crossref citations
Login to your personal dashboard for more detailed statistics on your publications.
Access personal reportingEdited by Lorenzo Galati Giordano
By Rausley Adriano Amaral de Souza, Dayan Adionel Guimarães and André Antônio dos Anjos
Edited by Marcello Chiaberge
By M.A.Kalam and H.H. Masjuki
We are IntechOpen, the world's leading publisher of Open Access books. Built by scientists, for scientists. Our readership spans scientists, professors, researchers, librarians, and students, as well as business professionals. We share our knowledge and peer-reveiwed research papers with libraries, scientific and engineering societies, and also work with corporate R&D departments and government entities.
More About Us