 Research
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Modelbased variables for the kinematic assessment of upperextremity impairments in poststroke patients
Journal of NeuroEngineering and Rehabilitation volume 13, Article number: 81 (2016)
Abstract
Background
Common scales for clinical evaluation of poststroke upperlimb motor recovery are often complemented with kinematic parameters extracted from movement trajectories. However, there is no a general consensus on which parameters to use. Moreover, the selected variables may be redundant and highly correlated or, conversely, may incompletely sample the kinematic information from the trajectories. Here we sought to identify a set of clinically useful variables for an exhaustive but yet economical kinematic characterization of upper limb movements performed by poststroke hemiparetic subjects.
Methods
For this purpose, we pursued a topdown modeldriven approach, seeking which kinematic parameters were pivotal for a computational model to generate trajectories of pointtopoint planar movements similar to those made by poststroke subjects at different levels of impairment.
Results
The set of kinematic variables used in the model allowed for the generation of trajectories significantly similar to those of either subacute or chronic poststroke patients at different time points during the therapy. Simulated trajectories also correctly reproduced many kinematic features of real movements, as assessed by an extensive set of kinematic metrics computed on both real and simulated curves. When inspected for redundancy, we found that variations in the variables used in the model were explained by three different underlying and unobserved factors related to movement efficiency, speed, and accuracy, possibly revealing different working mechanisms of recovery.
Conclusion
This study identified a set of measures capable of extensively characterizing the kinematics of upper limb movements performed by poststroke subjects and of tracking changes of different motor improvement aspects throughout the rehabilitation process.
Background
Upper limb functions are altered in about 80 % of acute stroke survivors and in about 50 % of chronic poststroke patients [1]. With the increasing of life expectancy, it has been estimated that stroke related impairments will be ranked to the fourth most important causes of adult disability in 2030 [2], prompting the need to design more effective diagnostic and rehabilitative tools [3, 4].
Together with more traditional and widely accepted clinical scales in the last two decades investigators have characterized poststroke motor recovery also in terms of kinematic parameters extracted from hand and arm taskoriented movements [3, 5], which offer more objective measures of motor performance [6]. Indeed, clinical scales, whose reliability has often been questioned [7–9], may not be sensitive to small and more specific changes [10] and could be of limited use to distinguish different aspects of motor improvement [11, 12].
Previous robotassisted clinical and pilot studies have proposed a large set of kinematic parameters to characterize motor improvements [5, 6, 11]. A few of them focused on finding a significant relationship between robotic measures collected longitudinally in poststroke patients and clinical outcome measures, to increase acceptance of kinematic evaluation scales in practice [5, 6]. Too little effort, however, has been made to identify the different aspects of movement improvement, how they can be described by kinematic robotbased measures [11], and whether they may dissociate with respect to recovery time course and to training response [11].
Indeed the range of potential changes in limb trajectory during recovery is not known a priori [12] and might not be fully represented by a set of arbitrarily selected parameters extracted from limb trajectories, even if the parameters were chosen according to a certain number of study hypotheses or to significant relationships with clinical scales. Moreover, these variables can be highly correlated and, thus, redundant. Although redundancy can be tackled by data reduction algorithms, such as Principal Component Analysis (PCA) or Independent Component Analysis (ICA) [5, 6], incomplete representation of information might still remain an overlooked issue.
In the present study we aimed at devising a novel method for identifying a set of kinematic measures potentially capable of fully highlighting and tracking changes of different aspects of movement performance throughout the rehabilitation training. Instead of starting from a certain number of a priori hypotheses, we sought to find which variables were essential for modeling trajectories of poststroke patients and were, thus, informative of kinematic features of upper limb movements. We then tested whether the identified kinematic parameters i) were capable of highlighting changes in movement performance, ii) were to some extent redundant, and iii) were informative of different factors of poststroke motor impairment, such as paresis, loss of fractionated movement and somatosensation, and abnormal muscle tone [13].
Methods
Participants
The data from 12 patients (6 men 6 women) were included in this study. All patients experienced a single unilateral cerebrovascular accident. 6 patients (subacute, age 71.8 ± 5.4 years) were enrolled less than 40 days after stroke, and 6 patients (chronic, age 64.0 ± 12.9 years) between 5 and 142 months poststroke. Participants’ FuglMeyer Assessment (FMA) scores [14, 15] were 20.5 ± 9.0 and 27.5 ± 8.7 for subacute and chronic patients, respectively. Table 1 reports a summary of the features related to all patients at the beginning of the therapy. Data related to the subacute patients and details on the rehabilitation protocol were already reported in a previous study [16].
Due to the limited sample size the inhomogeneity in the patient groups and in the treatment schedules (see Rehabilitation protocol), motor performances will not be compared between the two stroke survivor populations.
Seven neurologically intact agematched subjects (5 men 2 women; age 72 ± 5 years) were also included in the study as control group (part of their data were published earlier [17]). Healthy participants exhibited normal ranges of motion and muscle strength and they did not show any functional disability.
Rehabilitation protocol
The patients and the healthy subjects were instructed to make pointtopoint reaching movements forward and backward from the center of the workspace to one of eight different targets equally spaced around a circle of 14 cm of radius (Fig. 1 step 1) assisted by InMotion2 (Interactive Motion Technologies, Inc. Cambridge, Massachusetts) [18]. When the subjects sequentially carried out all the 16 movements, they completed one full turn.
The rehabilitation protocol consisted of 45 min of robotassisted therapy (at least 65 turns per sessions) five days per week. Subacute patients practiced for 6 weeks whereas chronic patients for 4 weeks. The difference in the treatment schedules was due to the organizational structure of the hospital in which the treatment was carried out. The robot provided assisting force when patients were not able to reach the targets, except for 2/3 turns per session (i.e., assessing turns) that were used to assess subjects’ motor performance. In this study, only the data related to these assessing turns and the data recorded without application of external force fields for the healthy subjects were included. The protocol was approved by the Local Ethical Committee (Comitato Etico Azienda Ospedaliera Universitaria di Pisa. Reference N°: 2754, year 2009).
Participants’ upper limb motor functions were evaluated before (T _{ 0 }) and after (T _{ 1 }) the rehabilitative treatment by an experienced physiatrist using clinical scales: FMA [14, 15], Modified Ashworth Scale (MAS) for shoulder and elbow [19], and Motricity index (MI) [20].
Computational model
We devised a computational model able to simulate endpoint planar trajectories of stroke patients for the given upperlimb rehabilitation protocol (see Rehabilitation protocol) starting from the knowledge of a limited number of kinematic parameters (i.e., Modelbased parameters), whose values were specified according to the experimental data (i.e., extracted from the real trajectories of the poststroke patients included in this study). Indeed, simulated trajectories geometrically similar to those of stroke patients, and with comparable kinematic features, would imply that the Modelbased parameters are a thorough and yet parsimonious way to represent the kinematic information contained in the trajectories of poststroke subjects.
Unlike previous studies [21, 22], pointtopoint movements were modeled specifying the complete trajectory on the plane. Indeed, unidimensional models are suitable for modeling healthy adult movements, which are approximately straight in the Cartesian space [21, 23], but inevitably they neglect to characterize the deviations from the theoretical path (i.e., the straight line connecting the start and the target points), which are indeed important markers of motor improvements of poststroke patients.
We started by modeling the time profile of a trajectory’s tangential speed v _{ T } (t), as a sum of submovement curves (i.e., single discrete movements that contribute to the resulting movement path, Fig. 1, step 3):
such that:
0 ≤ t ≤ t,
\( \frac{1}{\boldsymbol{t}}{\displaystyle {\int}_0^{\boldsymbol{t}}v(t)dt=MV,} \)
E[σ] = < σ>.
These curves were assumed to be bellshaped Gaussian profiles centered at time t _{ i } with amplitude A _{ i } _{ i } and duration proportional to σ _{ i }. Indeed, Krebs et al. [24] demonstrated that submovement speed profiles are remarkably similar across patients even though neurological damages are not, and can be appropriately approximated by nearly symmetrical βfunctions or by Gaussian curves. The peak times, t _{ i }, in the tangential speed profile were randomly drawn from a uniform distribution U (0,t), with the constraint of being spaced at least by 2<σ> to avoid peak overlapping, and σ _{ i } were randomly chosen such that E[σ] = <σ>.
This v _{ T } (t) profile model requires the specification of the number of submovements of which the entire movement is composed of i.e., n = −nPK, their average peak duration <σ>, the movement duration, t, and the average tangential speed, MV. To generate simulated v _{ T } (t) profiles specific for each patient group (subacute, chronic) and time point during the therapy (T _{ 0 }, T _{ 1 }), we first extracted the values of nPK, <σ>, t, MV from the trajectories recorded during the experiments (Fig. 1, step 2). In particular, nPK was obtained with the constraint that peaks amplitude had to be larger than the 10 % of the maximum speed amplitude [25] and <σ> was computed as the average σ of the Gaussian curves fitted to each tangential submovement.
We then estimated different (for each patient group and time point) probability distributions for these parameters (pooling data across repetitions subjects, and movement directions). A new random sample from each distribution was drawn each time a new simulated tangential speed profile had to be generated. The new simulated tangential speed profile was computed by solving a numerical optimization problem (constrained problem with the active set algorithm implemented in the function fmincon) in Matlab (Mathworks, Inc., MA, USA):
subject to the constraint:
The problem of generating simulated twodimensional trajectories required the specification of endpoint motion in two axes on the plane of movement. We chose the axis defined by the theoretical path and the corresponding orthogonal axis (the L and N axes respectively, in Fig. 1, step 4). The endpoint motion was specified in terms of the projections of the velocity vector, v (t), along these two axes: the longitudinal, v _{ L } (t), and the transversal, v _{ N } (t), speed profiles. This problem cannot be solved analytically because v _{ T } (t) did not contain information regarding the direction of the movement, thus a number of assumptions were made to obtain approximated solutions for v _{ L } (t) and v _{ N } (t).
First similar to v _{ T } (t), we assumed that v _{ L } (t) and v _{ N } (t) were composed of a sum of Gaussian bellshaped curves. Indeed, these curves represent submovements projected onto orthogonal directions: the longitudinal, L, and the transversal, N, axes (see Fig. 1, step 4). Moreover, the correlation between a fitted sum of Gaussian bellshaped curves with the experimental longitudinal and transversal speed profiles was high (Pearson’s correlation: ρ = 0.75 ± 0.18).
Second we considered that a number of peaks in v _{ T } (t) could be the result of movements traveling predominantly in the longitudinal or transversal direction. To take this into account, two additional parameters were added to the model: CONT _{ L } and CONT _{ N }, i.e. the number of peaks in v _{ L } (t) and v _{ N } (t), respectively, producing a corresponding peak in v _{ T } (t). CONT _{ x } (\( \mathrm{with}x\in \left\{L,N\right\} \)) was calculated on the longitudinal or the transversal speed profile of each experimental trajectory as the sum of “contributing peaks”, i.e. peaks falling within a time interval as large as σ and centered on peaks of the tangential velocity. For v _{ L } (t) and v _{ N } (t), the number of peaks (i.e., nPK _{ L } and nPK _{ N, } respectively) were calculated following the same technique used for v _{ T } (t) considering separately the positive and the negative part of the speed profile, resulting in the estimation of positive and negative peaks, respectively.
Third nPK _{ L } and nPK _{ N } were assumed to be comparable because they had, on average, similar values in our dataset (except for subacute patients at T _{ 0 } ; p = 0.04 Wilcoxon rank sum test, significance level α = 0.05) and were computed from the rationPK (ratio between the number of peaks in the longitudinal and in the tangential velocity profiles). However, should this assumption be falsified in a new cohort of patients larger than ours, the model could be easily modified to include both nPK _{ L } and nPK _{ N } in the Modelbased parameters.
The longitudinal and transversal speed profiles can be expressed similarly to v _{ T } (t) (see Eq. 1) with t ^{(x)}_{ i } and A _{ i } ^{(x)}_{ i } the central instants and amplitudes of the peaks in the speed profile with x ∈ {L, N}. A number of CONT _{ x } central instants were the same at which peaks in v _{ T } (t) occur, whereas the remaining nPK _{ x }  CONT _{ x } were randomly chosen in [0, t], with a constraint on peaktopeak distance similar to that for v _{ T } (t):
such that:
0 ≤ t ≤ t,
\( \frac{1}{\boldsymbol{t}}{\displaystyle \underset{0}{\overset{\boldsymbol{t}}{\int }}}v(t)dt=M{V}_x, \)
E[σ] = <σ>.
with x ∈ {L, N}. The computation of the two velocities can be reduced to a single unconstrained optimization problem to find the amplitudes \( \left[{A}_i^{(L)}\dots {A}_{{\mathbf{nPK}}_{\mathbf{L}}}^{(L)},\kern0.5em {A}_i^{(N)}\dots {A}_{{\mathbf{nPK}}_{\mathbf{N}}}^{(N)}\right] \) (see Fig. 1 step 5). Initial values for these amplitudes were set by using two additional parameters: ratioamp _{ L }, the ratio between average longitudinal and average tangential peak amplitude, and ratioamp _{ N } (i.e., same parameter with the average transversal peak amplitude in the numerator). Specifically, the function to minimize was:
with α and β two parameters (α, β ≤ 1) whose values were chosen to obtain a solution v = (v _{ L } (t), v _{ N } (t)) meeting the requirements for MV_{L} and MV_{N} (i.e., average v _{ L } (t) and v _{ N } (t), respectively) at different compliance levels. In our simulations we used α = 0.8 and β = 0.2.
The generation of v _{ L } (t) and v _{ N } (t) starting from the peaks (timing and amplitude) in the tangential velocity (that indicate changes in 2D movement direction and then determine 2D shape) allows the model to preserve the link between longitudinal and transversal speed components which was present also in the real trajectories (see Additional file 1: Figure S1 for a comparison of correlation values between longitudinal and transversal components in simulated and real trajectories).
As for the tangential speed the values of the six parameters required for the generation of simulated v _{ L } (t) and v _{ N } (t) (MV _{ N, } CONT _{ L }, CONT _{ N }, ratioamp _{ L }, ratioamp _{ N, } rationPK) were extracted from the trajectories recorded during the experiments, and subsequently pooled to estimate probability distributions, which were specific for each patient group and time point during the therapy (Fig. 1, step 2 and step 4). MV _{ L } was not directly estimated from the experimental trajectories but calculated as the ratio between the distance centertarget, D = 14 cm, and the overall (experimental) duration of the movement, t.
Once the speed profiles were computed (by solving an unconstrained optimization problem with the active set algorithm implemented in the function fminsearch of Matlab) they were numerically integrated over time to obtain the trajectory components along the longitudinal and transversal directions: x _{ L } (t) and x _{ N } (t), respectively (see Fig. 1, step 6). Finally, the two trajectory components were rotated to express the simulated endpoint trajectory in the InMotion2 coordinate frame (see Fig. 1, step 7).
Sensitivity analysis was performed to demonstrate the stability of the model: for both group of patients and time points (T _{ 0 } and T _{ 1 }) a parameter at a time was varied (ten variations equally distributed across its probability distribution) while keeping the other parameters fixed at the average value of their probability distribution. Results of sensitivity analysis were comparable to those found with the parameters values chosen showing that the model was robust for variation of the parameters (see Additional file 2: Figure S2).
Model validation
The mean Euclidean distance normalized by the total distance traveled during the reaching movement was used to assess the geometrical similarity between real and simulated trajectories E _{ RS }. Simulated trajectories were considered similar to the real ones if the range of variation of E _{ RS } was comparable to E _{ I } ^{(R)}, i.e., the intrinsic trajectory variability (intersubject and intrasubject) of real curves.
We then validated the ability of the simulated trajectories to capture significant kinematic features of real movements by comparing the values of an extensive set of additional kinematic parameters not used by the model, computed on both simulated and real trajectories. This set of parameters was chosen to extensively characterize longitudinal and transversal speed profiles and to check the suitability of the optimization strategies used to simulate the speed profiles (i.e., tangential, longitudinal, and transversal) and, consequently, the trajectories. The following parameters (i.e., Evaluation parameters) were considered: MV _{ L }, average longitudinal speed; A average amplitude of peaks in v _{ T } (t); A _{ L } –pos and A _{ L } –neg (A _{ N } –pos and A _{ N } –neg) average amplitude of positive and negative peaks for v _{ L } (t) (v _{ N } (t)); nPK _{ L } –pos and nPK _{ L } –neg (nPK _{ N } –pos and nPK _{ N } –neg) the number of positive and negative peaks for v _{ L } (t) (v _{ N } (t)); CONT _{ N } amp the ratio between the average transversal and tangential peak amplitudes, computed only for “contributing” peaks; CONT _{ L } amp similar parameter for v _{ L } (t); MD the mean absolute value of the distance between the actual trajectory and the theoretical path; overlap the overlapping area between two submovements (intersection between the two Gaussian curves describing the submovements normalized by the sum of the two areas).
As a further validation of the model we tested the similarity between shoulder and elbow angular excursions computed from the simulated and the real trajectories using the twolink model for upperlimb movements introduced in [25]. Indeed, previous studies evaluated shoulder and elbow angular excursions during different tasks and reported an abnormal joint coupling in poststroke patients that reduces during rehabilitative treatment [26–28].
Joint angles were estimated as:
where θ_{1} and θ_{2} are respectively shoulder and elbow joint angles \( \mathrm{k}=\sqrt{{\left({\mathrm{x}}^2+{\mathrm{y}}^2+{\mathrm{l}}_1^2+{\mathrm{l}}_2^2\right)}^22\Big[{\left({\mathrm{x}}^2+{\mathrm{y}}^2\right)}^2+{\mathrm{l}}_1^4+{\mathrm{l}}_2^4}\Big],\uppi \le { \tan}^{1}\le \uppi, {\mathrm{l}}_1 \) is the upper arm length, and l_{2} the lower arm length. Values of the parameters l_{1} and l_{2} were estimated both for simulated and real trajectories from the measurements of the 50th percentile for U.S. males [29]: l_{1}was estimated as 0.282 m; whereas l_{2} was calculated as the sum of forearm length (0.254 m) the distance from the wrist to the handle (0.076 m), and the handle robot radius (0.03 m).
Joint angular excursions computed from the simulated and the real trajectories were compared using d _{ % } (the average distance between two angular trajectories resampled to the same number of time points and normalized by the maximum angular excursion of the real trajectory).
Investigation of underlying factors of motor recovery
Finally we inspected the Modelbased parameters both to evaluate redundancy among the parameters and to find whether longitudinal variations in these variables might have been explained by a restricted number of underlying (and unobserved) factors, putatively reflecting different aspects of motor recovery [11]. For this purpose, we performed a Factor Analysis (FA) with Maximum Likelihood extraction and promax rotation method on the Modelbased parameters. These were pooled from all movement directions and repetitions for healthy subjects and patients at each day of rehabilitation. The number of retained factors was selected on the basis of “cleanliness of factor structure”, and both the individual (>5 %) and the cumulative percentage (≥70 %) of total variance explained [30]. For each factor, the parameters with loadings >0.6 were clustered together [30]. Variables with loadings not exceeding the threshold for none of the factors were named “shared”. To determine the time course of each factor along the rehabilitation process, for each patients group separately, we fitted the data to different functions: straight line, exponential decay, and doubleexponential decay. The best fit was then selected among these three functions according to the Bayesian Information Criterion (BIC) [31].
Statistical analyses
Comparisons between T _{ 0 } and T _{ 1 } clinical scores and kinematic parameters were made with a Wilcoxon signedrank test (significance level α = 0.05), for the two groups of patients separately. Parameters from real and simulated trajectories were analyzed separately. E _{ RS } values were compared with the intrinsic variability of the real trajectories, E _{ I } ^{(R)}, for both groups of patients and time points (T _{ 0 } and T _{ 1 }) using a Wilcoxon rank sum test (significance level, α = 0.05).
Results
Simulated trajectories reliably approximated real trajectories of poststroke subjects
Simulated trajectories were generated for subacute and chronic patients both at time T _{ 0 } and T _{ 1 } (Fig. 2). As explained in Methods (Computational model) our aim was not to precisely reconstruct real trajectories, but to generate simulated trajectories consistent with the real ones. Indeed, simulated trajectories showed significant geometrical similarity with the real trajectories. In fact, the range of variation of E _{ RS } was comparable to the intrinsic trajectory variability of real curves, E _{ I } ^{(R)}, both at T _{ 0 } and T _{ 1 }. The average E _{ RS } (across movement directions and subjects) was 14.52 ± 0.78 % at T _{ 0 } and 13.02 ± 0.52 % at T _{ 1 }, for subacute patients, and 16.88 ± 1.43 % at T _{ 0 } and 13.05 ± 1.25 % at T _{ 1 }, for chronic patients. Comparable ranges were confirmed by statistical tests. Indeed, only E _{ RS } for subacute patients at T _{ 1 } was higher than E _{ I } ^{(R)} (p = 0.008).
Interestingly E _{ I } ^{(R)} decreased after therapy, showing a reduction of performance variability within each group of patients, which was correctly captured by our model in the case of chronic patients (E _{ I } ^{(R)}: 15.71 ± 2.87 % at T _{ 0 } and 9.90 ± 2.43 % at T _{ 1 }, for subacute; 15.61 ± 3.38 % at T _{ 0 } and 11.87 ± 2.18 % at T _{ 1 } for chronic; E _{ I } ^{(S)}: 10.70 ± 1.18 % at T _{ 0 } and 13.88 ± 1.05 % at T _{ 1 } for subacute; 16.65 ± 1.48 % at T _{ 0 } and 11.71 ± 2.60 % at T _{ 1 } for chronic).
Finally the similarity between real and simulated angular excursions (elbow and shoulder) was assessed (see Fig. 3). The low d _{ % } values between simulated and real angular trajectories (19 % for the shoulder and 5 % for the elbow, on average) showed that joint movements of poststroke subjects were also finely reproduced.
Taken together these results demonstrated that the proposed computational model was able to simulate trajectories similar to those observed in poststroke subjects at different impairment levels, both in the Cartesian and in the joint spaces.
Modelbased parameters represents kinematic features of poststroke trajectories
Although measuring motor improvements by means of clinical scales was not one of the main aims of this study we reported the scores of both subacute and chronic patients after therapy for the purpose of observing parallel significant improvements in both clinical scales and kinematic measures from pointtopoint upper limb movements (Fig. 4a). The clinical scores partially correlated. In particular MAS score for the shoulder and the elbow correlated significantly (r = 0.85, p < 0.001), as well as FMA score and Motricity index (r = 0.88, p < 0.001). Moderate correlation between the ability to perform isolated joint movements (FMA score) and upperlimb strength (Motricity index) and, in contrast, low correlation with MAS score (r = 0.14, p >0.05), were in agreement with previous work [6, 32].
We quantified movements’ improvements by computing both the Modelbased and the Evaluation parameters on patients’ trajectories (Fig. 4b and Additional file 3: Figure S3).
Subjects’ movement duration t, significantly diminished both for subacute and chronic patients across training sessions (p < 0.05). The movement smoothness (nPK) and MV _{ N }, instead, increased significantly along the treatment in both groups, whereas MV only in subacute patients (p < 0.05). Consistently with the increase of the mean velocity, a slight increment in longitudinal peaks amplitude (ratioamp _{ L }) and a significant decrease in transversal peaks amplitude (ratioamp _{ N }) were observed (p < 0.05), indicating a progressive translation of submovements toward the longitudinal direction. The increase in movement smoothness, instead, was reflected in a significant reduction of both longitudinal (CONT _{ L }, p < 0.05 for subacute patients) and transversal peaks contribution (CONT _{ N }, p < 0.05 both for subacute and chronic patients). Interestingly, rationPK had only a slight increase during the therapy, but it reached values comparable to those observed in the healthy subjects. Finally, the significant rise in both patient groups of the σ values (p < 0.05) revealed an increment of submovements’ duration, which, together with improved smoothness and increased overlap (Additional file 3: Figure S3), was consistent with the proposed mechanism of submovements blending during recovery [3]. All parameters values except rationPK and <σ> were significantly different (p < 0.003) between poststroke and healthy subjects at T _{ 0 } and T _{ 1 }, showing that albeit there were significant motor improvements in upper limb movements, the patients’ recovery was not complete.
We then investigated whether the kinematic features of real trajectories (and their evolution during the rehabilitation process) were well reproduced by simulated trajectories by comparing the values of the Evaluation parameters calculated on both trajectory types at T _{ 0 } and T _{ 1 } (Modelbased parameters were used for the generation of the simulated trajectories as explained in section 2.3, and could not be used for the purpose of model evaluation). The Evaluation parameters were chosen because they were not directly linked to the Modelbased parameters by means of known mathematical relationships. Indeed, only nPK _{ x } –pos and nPK _{ x } –neg (with x ∈ {L, N}) correlated with nPK and CONT _{ x } (on average: r = 0.91, p < 0.001, Additional file 4: Figure S4A), and MV _{ L }, A, A _{ L } –pos, A _{ L } –neg with MV (on average: r = 0.94, p < 0.001).
The model was able to reproduce both values and trends (between T _{ 0 } and T _{ 1 }) in the vast majority of the Evaluation parameters (Additional file 3: Figure S3 comparison between gray and colored bars). In particular, movement speed increased, as already showed by the Modelbased parameters and further supported by the significant increase in MV _{ L }, A, A _{ L } –pos, and A _{ L } –neg for real and simulated trajectories both for subacute and chronic patients (p < 0.05). Amplitude of transversal peaks (A _{ N } –pos and A _{ N } –neg), instead, significantly increased for subacute patients and decreased for chronic patients (p < 0.05). The simulations also reproduced a raise in the movement smoothness, which was accompanied by a significant reduction of positive and negative peaks both for transversal and longitudinal velocities (nPK _{ L } –pos, nPK _{ L } –neg, nPK _{ N } –pos, and nPK _{ N } –neg) (p < 0.05). Finally, MD significantly decreased between T _{ 0 } and T _{ 1 } for both patient groups (p < 0.05). This decrease could be explained by a translation of the movements toward the longitudinal direction as supported from the increment of CONT _{ L } amp and the reduction of CONT _{ N } amp.
Different aspects of motor recovery highlighted by the modelbased parameters
When looking at internal correlations within the Modelbased parameters (Fig. 5a) we observed that nPK was highly correlated with t (r = 0.94, p < 0.001), in agreement with [10], suggesting that submovement blending was strictly intermingled with movement duration shortening. Other parameters, computed on transversal and longitudinal velocities, such as <σ>, rationPK, ratioamp _{ L }, and ratioamp _{ N }, instead, were not correlated with the others (on average: r = 0.24, p > 0.05), suggesting that they were likely representing different aspects of motor improvements.
When FA was used to inspect for redundancy among the Modelbased parameters and to investigate more in detail the different factors involved in motor recovery and particularly which variables measured similar aspects of motor improvement, three main factors were found, explaining together 70 % (52 %, 12 %, and 6 %, respectively) of the total variance (Fig. 5b). The first major factor decreased during the rehabilitation, was related to variables mainly accounting for movement inefficiency (nPK, CONT _{ L }, CONT _{ N }, and t), and correlated with FMA score (r = 0.60, p = 0.002, Fig. 5c). The second factor increased during the rehabilitation, was related to MV and MV _{ N } (movement speed), and correlated with MAS score for the shoulder (r = 0.68, p < 0.001). Finally, the third factor correlated with FMA score (r = 0.50, p = 0.015) and was described by ratioamp _{ N, } which relates to movement inaccuracy as detailed by the high correlation with MD (r = 0.68, p < 0.001).
Interestingly the temporal dynamics during the therapy was different for the three factors (Fig. 5d) suggesting different central and/or peripheral mechanisms concurrently involved in patients’ motor recovery, each with a specific temporal scale. In particular, for subacute patients the first and the third factors showed a doubleexponential decay, with a comparable fast component (τ ≈ 0.5 and 0.3, respectively), which was even faster than the increase of movement speed (τ ≈ 2.5 sessions). The slow component, instead, had a larger decay time constant for movement inaccuracy (τ ≈ 10 sessions) than for inefficiency (τ ≈ 5.6 sessions), i.e., inaccuracy was the slowest to reach a plateau in its temporal evolution during rehabilitation. The best fit for the time courses of the three factors for chronic patients were straight lines. The slopes values revealed a mild decrease for movement inefficiency (m ≈ −0.005) over rehabilitation, and a more evident increase for movement speed (m ≈ 0.03) and decrease for inaccuracy (m ≈ −0.05).
Discussion
In this study we introduced a computational model of trajectory generation to identify a set of ten variables, the Modelbased parameters, which allow for an exhaustive kinematic characterization of upperlimb planar movements performed by poststroke hemiparetic subjects during robotbased training. We then demonstrated that these parameters are informative of three main underlying (and unobserved) recovery factors (movement inefficiency, speed, and inaccuracy), each one characterized by a specific time evolution, and, thus, putatively revealing a different central and/or peripheral mechanism of motor restoration.
A computational model of poststroke subjects’ trajectories
Previous computational models of trajectory generation in healthy adult subjects include motor control strategies explained by minimum variance [33] minimum jerk [34], minimum torque change [35], and optimal feedback control [36]. However, motor control strategies are often modified by brain insults [37, 38] reflecting the need for tampered computational models. Therefore, in order to generate poststroke trajectories, we designed a model based on the wellknown mechanism of submovement blending [3]. Indeed, in our model, tangential speed profiles of pointtopoint movements were assumed to be a sum of submovement curves with bellshaped Gaussian profiles, i.e., the tangential speed profile was composed of a finite sum of submovements with similar shapes but dilated in duration, translated in time, and modulated in amplitude. A previous work has demonstrated that submovement speed profiles from stroke patients can be appropriately approximated by nearly symmetric βfunctions, and that the differences with Gaussian curves were rather minimal [24]. We, therefore, used Gaussian curves for tangential speed and extended this assumption also to transversal and longitudinal velocity profiles. These results would require further experimental validation on a larger population of stroke subjects.
The simulated trajectories generated by our computational model were significantly similar to the real trajectories from poststroke patients and were able to reproduce the trends in the Evaluation parameters. These results demonstrated the capability of the Modelbased parameters to well characterize the kinematics of patients’ movements and to discriminate between different impairment levels. Additionally, small differences were found between real and simulated angular excursions of limb joints, indicating that impairments at the joint level are influenced by the number and amplitude of peaks in both the transversal and longitudinal speed components. However, the angular excursions at the elbow were better reproduced than those at the shoulder (5 % versus 19 %), probably because of the twolink model limitations to reconstruct shoulder movements normally characterized by three degrees of freedom [25].
Our computational model is currently limited to simulate trajectories of movements autonomously performed by poststroke subjects which could restrict the applicability of the proposed framework to patients with moderate to mild impairments. Indeed, patients with more severe functional damages most often require robot assistance to accomplish the task [39]. Future works are recommended to address this issue, and to extend the model to other volitional arm movements and assistive devices, such as exoskeletons [40–43]. Indeed, exoskeletons offer several advantages over planar manipulandum because they enlarge the task space to three dimensions following the arm in its natural workspace with no restrictions [44]. Therefore, an extension of our model to threedimensional trajectories would be of interest for further applications.
Interestingly this model could represent an element of a larger framework for testing new solutions for the reinforcement and the personalization of the therapy [45]. Simulated trajectories could be used to assess whether the patient’s movements follow the expected improvement, thus prompting ‘realtime’ clinical actions. Indeed, the values of Modelbased parameters computed from real trajectories at T _{ 0 } and the estimates of motor improvement trends along the rehabilitation training could be fed to the model and used to generate reference trajectories for a given rehabilitation session. Upon comparing these trajectories with the real ones from the patient, actions for task assistance could be immediately triggered, and training refinement could be rightly planned and implemented.
Modelbased kinematic parameters of pointtopoint trajectories
Four variables used by the model: MV nPK, <σ>, and t, are wellknown parameters proposed by a number of previous studies to characterize motor improvements in poststroke subjects [5, 39, 46, 47]. They are extracted from the tangential speed profile and they neglect aspects of motor improvement related to endpoint accuracy and directional errors. For this reason, they are often complemented by other measures to achieve a more exhaustive description of motor improvement. These additional parameters (e.g., the “mean distance from theoretical path”, the “trajectory straightness”, etc. [47, 48]), however, require a priori assumption that pointtopoint movements from fully recovered patients, as well as from healthy subjects, are straight, which might be ultimately wrong [49]. Instead, here, we proposed new variables computed from the transversal and longitudinal speed profiles that do not require a priori assumptions on movement straightness.
Among these new parameters MV _{ N }, CONT _{ N, } and ratioamp _{ N } were initially considered putative parameters to assess movement accuracy, because they were computed from submovements transversal to the theoretical path. However, only ratioamp _{ N } was highly correlated with MD, a wellknown measure of movement accuracy [39, 47], whereas CONT _{ N } turned out to be negatively correlated with nPK, and MV _{ N } positively correlated with MV. The latter was rather unexpected and counterintuitive, because a reduction of average movement speed in the transversal direction was expected, based on the welldocumented tendency of poststroke trajectories to become straighter with training [49]. Instead, MV _{ N } increased in parallel with MV, presumably reflecting improved general muscle tone as also demonstrated by the correlation with the MAS score for the shoulder (r = 0.50, p = 0.002, see Additional file 4: Figure S4B) [11]. The increase of accuracy, instead, was probably obtained by reducing the speed of transversal submovements with respect to longitudinal movements, a complex strategy most likely planned and realized by more central mechanisms involved in motor recovery.
Taken together these new insights significantly contribute to expand the current theory of poststroke motor recovery based on discrete submovements blending [3].
Kinematic markers of motor recovery
In our cohort of patients the evaluation of the clinical scales at time T _{ 0 } and T _{ 1 } showed that robotaided therapy led to a reduction of impairment in the hemiparetic limb. This was paralleled by improvements in pointtopoint upper limb movements which became progressively similar to those of healthy subjects. We here have to acknowledge the limited sample size of the two patient groups that reduces the strength of the statistical findings. However, the study in which the patients were enrolled was designed as a pilot study [16] with the straight restriction to recruit patients with absence of bilateral impairments.
The application of Factorial Analysis to the Modelbased parameters showed that the latter were redundant to some extent and informative of three main recovery factors.
The first factor named movement inefficiency, was mainly related to variables describing temporal efficiency (movement duration) and movement smoothness. This result confirms and reinforces the quantitative analysis made by Alt Murphy et al. [10] and it advises a reinterpretation of previous disentanglement between these two variables into two different aspects of movement impairments: paresis (i.e., the decreased ability to volitionally modulate motor units activation [13]) and abnormal muscle tone [11]. Moreover, this result suggests that submovement blending, which caused improved movement smoothness, was also one of the main causes of movement duration shortening. The second factor, movement speed, was intimately related to muscle tone [11], whereas the third factor (i.e., movement inaccuracy) was mainly associated to the decrease of position errors along the primary axis of movement and, thus, to the loss of fractionated movement [11]. The decrease of the fast component of the first and third factors was slightly faster than the increase of movement speed. The slow component, instead, was slower for both factors, particularly for movement inaccuracy, which was the slowest to reach a plateau in its temporal evolution during rehabilitation. Similar temporal evolutions of the three factors during the rehabilitation process were visible also for chronic patients. However, the best fits for chronic patients were straight lines. Different evolution of the recovery factors could be already expected from the time course of the Modelbased parameters, which had a linear and exponential evolution for chronic and subacute patients, respectively (Fig. 4), and could be related to a more rapid and generalized improvement in early poststroke period, as suggested in [50], and to a different treatment length.
The importance of the Modelbased parameters as markers of motor recovery was highlighted also from the correlation with the different clinical scores (see Additional file 4: Figure S4B and 5c). In particular the Modelbased parameters correlated with the wellaccepted FMA score and the MAS score. Moreover, as expected from the assessment of the clinical scales, the first and the third factors correlated significantly with the FMA score, while the second factor had a significant correlation with the MAS shoulder score. Indeed, the FMA scale evaluates complex active movements that require the activation of several joints paralleling motor efficiency. The MAS scale, instead, evaluates the resistance to passive singlejoint movements and it could, thus, relate to the movement speed, which decreases with spasticity.
Conclusively the characterization of longitudinal and transversal velocities seems to be essential in clinical application for an exhaustive description of the patients’ motor impairments. The metrics proposed here could be used to complement therapists with immediate measures of motor performance [6] and to design more effective rehabilitation protocols targeted to differentially reduce gap performances in the two orthogonal directions. Interestingly, the existence of correlations among the Modelbased parameters, and particularly among the parameters related to movement inefficiency, and the fact that only three main factors of motor improvement were found by FA point to the possibility to further reduce the number of kinematic variables needed for a computational model to simulate strokelike trajectories. In this regard, a further study in a larger cohort of patients will be necessary to establish mathematical relationships among the Modelbased parameters, in order to further reduce their redundancy.
Conclusions
In this study, we defined a set of kinematic parameters for the characterization of upper limb movements performed by poststroke hemiparetic subjects during robotbased training. Despite the considerable development of robotassisted therapy in clinical practice and the various kinematic variables suggested so far, there is still no a general consensus on which parameters to use to evaluate the movement performance. The metrics proposed here are based on a modeldriven approach, rather than on specific study hypotheses or on sought relationships with clinical scales. We demonstrated that i) they capture relevant kinematic information to assess the quality of reaching trajectories; ii) they are manageable, i.e., they do not necessarily require data reduction techniques to extract information about movement performance from a large dataset of computed parameters; iii) they reveal diverse factors of kinematic improvement over time, which are informative of different central and/or peripheral mechanisms of motor recovery. By monitoring how these factors change over time at the individual level may provide a new tool to help physiotherapist to take decisions regarding treatment planning.
Abbreviations
 FA:

Factor analysis
 FMA:

Fuglmeyer assessment
 ICA:

Independent component analysis
 MAS:

Modified ashworth scale
 MI:

Motricity index
 PCA:

Principal component analysis
References
Gresham GE, Duncan PW, Stason WB. Poststroke rehabilitation. Darby: DIANE Publishing; 1997.
Donnan GA, Fisher M, Macleod M, Davis SM. Stroke. Lancet. 2008;371:1612–23.
Rohrer B, Fasoli S, Krebs HI, Hughes R, Volpe B, Frontera WR, Stein J, Hogan N. Movement smoothness changes during stroke recovery. J Neurosci. 2002;22:8297–304.
Patton J, Small SL, Zev Rymer W. Functional restoration for the stroke survivor: informing the efforts of engineers. Top Stroke Rehabil. 2008;15:521–41.
Krebs HI, Krams M, Agrafiotis DK, DiBernardo A, Chavez JC, Littman GS, Yang E, Byttebier G, Dipietro L, Rykman A. Robotic measurement of arm movements after stroke establishes biomarkers of motor recovery. Stroke. 2014;45:200–4.
Bosecker C, Dipietro L, Volpe B, Krebs HI. Kinematic robotbased evaluation scales and clinical counterparts to measure upper limb motor performance in patients with chronic stroke, Neurorehabilitation and neural repair. 2009.
Sanford J, Moreland J, Swanson LR, Stratford PW, Gowland C. Reliability of the fuglmeyer assessment for testing motor performance in patients following stroke. Phys Ther. 1993;73:447–54.
Krebs HI, Volpe BT, Ferraro M, Fasoli S, Palazzolo J, Rohrer B, Edelstein L, Hogan N. Robotaided neurorehabilitation: from evidencebased to sciencebased rehabilitation. Top Stroke Rehabil. 2002;8:54–70.
Gregson JM, Leathley MJ, Moore AP, Smith TL, Sharma AK, Watkins CL. Reliability of measurements of muscle tone and muscle power in stroke patients. Age Ageing. 2000;29:223–8.
Murphy MA, Willén C, Sunnerhagen KS. Kinematic variables quantifying upperextremity performance after stroke during reaching and drinking from a glass. Neurorehabil Neural Repair. 2011;25:71–80.
Nordin N, Xie SQ, Wünsche B. Assessment of movement quality in robotassisted upper limb rehabilitation after stroke: a review. J Neuroeng Rehabil. 2014;11:137.
Kitago T, Marshall RS. Strategies for early stroke recovery: what lies ahead? Curr Treat Options Cardiovasc Med. 2015;17:1–10.
Lang CE, Bland MD, Bailey RR, Schaefer SY, Birkenmeier RL. Assessment of upper extremity impairment, function, and activity after stroke: foundations for clinical decision making. J Hand Ther. 2013;26:104–15.
FuglMeyer AR. Poststroke hemiplegia assessment of physical properties. Scand J Rehabil Med Suppl. 1980;7:85.
FuglMeyer AR, Jääskö L, Leyman I, Olsson S, Steglind S. The poststroke hemiplegic patient. 1. a method for evaluation of physical performance. Scand J Rehabil Med. 1974;7:13–31.
Tropea P, Monaco V, Coscia M, Posteraro F, Micera S. Effects of early and intensive neurorehabilitative treatment on muscle synergies in acute poststroke patients: a pilot study. J Neuroeng Rehabil. 2013;10:103.
Cesqui B, Macrì G, Dario P, Micera S. Characterization of agerelated modifications of upper limb motor control strategies in a new dynamic environment. J Neuroeng Rehabil. 2008;5:31.
Krebs HI, Hogan N, Aisen ML, Volpe BT. Robotaided neurorehabilitation. IEEE Trans Rehabil Eng. 1998;6:75–87.
Bohannon RW, Smith MB. Interrater reliability of a modified ashworth scale of muscle spasticity. Phys Ther. 1987;67:206–7.
Collin C, Wade D. Assessing motor impairment after stroke: a pilot reliability study. J Neurol Neurosurg Psychiatry. 1990;53:576–9.
Burdet E, Milner TE. Quantization of human motions and learning of accurate movements. Biol Cybern. 1998;78:307–18.
Balasubramanian S, MelendezCalderon A, Burdet E. A robust and sensitive metric for quantifying movement smoothness. Biomed Eng IEEE Trans. 2012;59:2126–36.
Flash T, Hogan N. The coordination of arm movements: an experimentally confirmed mathematical model. J Neurosci. 1985;5:1688–703.
Krebs HI, Aisen ML, Volpe BT, Hogan N. Quantization of continuous arm movements in humans with brain injury. Proc Natl Acad Sci. 1999;96:4645–9.
Dipietro L, Krebs HI, Fasoli SE, Volpe BT, Stein J, Bever C, Hogan N. Changing motor synergies in chronic stroke. J Neurophysiol. 2007;98:757–68.
Ellis MD, Sukal T, DeMott T, Dewald JP. Augmenting clinical evaluation of hemiparetic arm movement with a laboratorybased quantitative measurement of kinematics as a function of limb loading. Neurorehabil Neural Repair. 2008;22:321–9.
Ellis MD, SukalMoulton T, Dewald JP. Progressive shoulder abduction loading is a crucial element of arm rehabilitation in chronic stroke. Neurorehabil Neural Repair. 2009;23:862–9.
Sukal TM, Ellis MD, Dewald JP. Shoulder abductioninduced reductions in reaching work area following hemiparetic stroke: neuroscientific implications. Exp Brain Res. 2007;183:215–23.
Diffrient N, Tilley AR, Bardagjy JC. Humanscale 1/2/3: a portfolio of information. Cambridge: MIT Press; 1974.
Osborne JW, Costello AB. Best practices in exploratory factor analysis: four recommendations for getting the most from your analysis. PanPacific Manag Rev. 2009;12:131–46.
Box J: Reinsel, editor. Time Series Analysis, Forecasting and Control. Englewood Clifs. NJ: Prentice Hall; 1994.
Wei XJ, Tong Ky, Hu Xl. The responsiveness and correlation between fuglmeyer assessment, motor status scale, and the action research Arm test in chronic stroke with upperextremity rehabilitation robotic training. Int J Rehabil Res. 2011;34:349–56.
Harris CM, Wolpert DM. Signaldependent noise determines motor planning. Nature. 1998;394:780–4.
Hogan N. An organizing principle for a class of voluntary movements. J 727 Neurosci. 1984;4:2745–54.
Uno Y, Kawato M, Suzuki R. Formation and control of optimal trajectory in human multijoint arm movement. Minimum torquechange model. Biol Cybern. 1989;61:89–101.
Todorov E, Jordan MI. Optimal feedback control as a theory of motor coordination. Nat Neurosci. 2002;5:1226–35.
Cheung VC, Piron L, Agostini M, Silvoni S, Turolla A, Bizzi E. Stability of muscle synergies for voluntary actions after cortical stroke in humans. Proc Natl Acad Sci U S A. 2009;106:19563–8.
Cheung VC, Turolla A, Agostini M, Silvoni S, Bennis C, Kasi P, Paganoni S, Bonato P, Bizzi E. Muscle synergy patterns as physiological markers of motor cortical damage. Proc Natl Acad Sci U S A. 2012;109:14652–6.
Colombo R, Pisano F, Micera S, Mazzone A, Delconte C, Carrozza CM, Dario P, Minuco G. Robotic techniques for upper limb evaluation and rehabilitation of stroke patients. Neural Syst Rehabil Eng IEEE Trans. 2005;13:311–24.
Nef T, Guidali M, Riener R. ARMin III–arm therapy exoskeleton with an ergonomic shoulder actuation. Appl Bionics Biomech. 2009;6:127–42.
Carignan C, Liszka M, Roderick S. Design of an arm exoskeleton with scapula motion for shoulder rehabilitation. In Advanced Robotics, 2005 ICAR’05 Proceedings, 12th International Conference on. IEEE; 2005. 524–531.
Perry JC, Rosen J Design of a 7 degreeoffreedom upperlimb powered exoskeleton. In Biomedical Robotics and Biomechatronics, 2006 BioRob 2006 The First IEEE/RASEMBS International Conference on. IEEE; 2006. 805–810.
Pirondini E, Coscia M, Marcheschi S, Roas G, Salsedo F, Frisoli A, Bergamasco M, Micera S. Evaluation of the effects of the Arm light exoskeleton on movement execution and muscle activities: a pilot study on healthy subjects. J Neuroeng Rehabil. 2016;13:1.
Milot MH, Spencer SJ, Chan V, Allington JP, Klein J, Chou C, Bobrow JE, Cramer SC, Reinkensmeyer DJ. A crossover pilot study evaluating the functional outcomes of two different types of robotic movement training in chronic stroke survivors using the arm exoskeleton BONES. J Neuroeng Rehabil. 2013;10:112.
Casadio M, Tamagnone I, Summa S, Sanguineti V. Neuromotor recovery from stroke: computational models at central, functional, and muscle synergy level. Front Comput Neurosci. 2013;7:97.
Colombo R, Pisano F, Micera S, Mazzone A, Delconte C, Carrozza MC, Dario P, Minuco G. Assessing mechanisms of recovery during robotaided neurorehabilitation of the upper limb. Neurorehabil Neural Repair. 2008;22:50–63.
Panarese A, Colombo R, Sterpi I, Pisano F, Micera S. Tracking motor improvement at the subtask level during robotaided neurorehabilitation of stroke patients. Neurorehabil Neural Repair. 2012;26:822–33.
Cirstea MC, Levin MF. Compensatory strategies for reaching in stroke. Brain. 2000;123(Pt 5):940–53.
Wisneski KJ, Johnson MJ. Quantifying kinematics of purposeful movements to real, imagined, or absent functional objects: Implications for modelling trajectories for robotassisted ADL tasks. J Neuroeng Rehabil. 2007;4:7.
Krakauer JW, Carmichael ST, Corbett D, Wittenberg GF. Getting neurorehabilitation right what can be learned from animal models? Neurorehabil Neural Repair. 2012;26:923–31.
Acknowledgements
We would like to thank all the volunteers enrolled in the study.
Funding
This work was partially supported by the Wyss Center for Bio and Neuroengineering, the MIRROR Project (Novel Approaches for RobotMediated NeuroRehabilitation) funded by a local Bank Foundation (Fondazione MPS), and by the RISDOM Project by the Government of Tuscany (Italy) and the Municipality of Peccioli (Italy). This work was supported by the RONDA Project, funded by Regione Toscana PAR FAS 2007–2013.
Availability of data and materials
Since the data used in this study were collected in a clinical trial including patients, the data will not be shared. The Matlab code of the model will be available upon request to the corresponding authors of this study.
Authors’ contributions
AP designed the model, analyzed data, and wrote the paper; EP designed the model, analyzed data, and wrote the paper; PT carried out experiments, and wrote the paper; BC carried out experiments, and wrote the paper; FP carried out experiments, and wrote the paper; SM designed the model, and wrote the paper. All authors read and approved the final manuscript.
Competing interests
The authors declare that they have no competing interests.
Consent for publication
All participants signed an informed consent to the use of all data collected during the experiment in scientific publications.
Ethics approval and consent to participate
All participants signed an informed consent in accordance with the policies about trials with human subjects before starting experimental and rehabilitation sessions. The protocol was approved by the Local Ethical Committee (Comitato Etico Azienda Ospedaliera Universitaria di Pisa. Reference N°: 2754, year 2009).
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Additional files
Additional file 1: Figure S1.
Angular plots of the average correlation between longitudinal and transversal components among repetitions of the model and among subjects for the 8 directions of movements for subacute patient at T _{ 0 } (first column) and T _{ 1 } (second column) and for chronic patients at T _{ 0 } (third column) and T _{ 1 } (fourth column). Dark and light gray lines code the values for simulated trajectories at T _{ 0 } and T _{ 1 }, dark and light red lines code the values for real trajectories of subacute patients at T _{ 0 } and T _{ 1 }, and dark and light blue lines code the values for real trajectories of chronic patients at T _{ 0 } and T _{ 1 }. For the simulated trajectories, the correlation was in average 0.60 ± 0.09 and 0.55 ± 0.07 for subacute patients at T _{ 0 } and T _{ 1 }, and 0.47 ± 0.07 and 0.62 ± 0.09 for chronic patients at T _{ 0 } and T _{ 1 } and was thus comparable to the values of the real trajectories (0.48 ± 0.07 for subacute at T _{ 0 }, 0.56 ± 0.08 for subacute patients at T _{ 1,}0.50 ± 0.05 for chronic at T _{ 0 }, 0.49 ± 0.05 for chronic patients at T _{ 1 }). Comparable values were confirmed by statistical tests (Wilcoxon rank sum test, α = 0.05). Indeed, only correlation values for simulated trajectories of chronic patients at T _{ 1 } were higher than those of the real trajectories (p = 0.009). In general, these results show that the 2D correlation between the two components (i.e., longitudinal and transversal) and, thus, the 2D shape of the simulated trajectories was preserved also after decomposition of the tangential velocity. (PDF 413 kb)
Additional file 2: Figure S2.
Results for the sensitivity analysis for subacute patient at T _{ 0 } (first column) and T _{ 1 } (second column) and for chronic patients at T _{ 0 } (third column) and T _{ 1 } (fourth column). In the yaxis the Modelbased parameters and in the xaxis the ten variations equally distributed across the probability distribution of each parameter. The average E _{ RS } was 13.74 ± 0.54 % at T _{ 0 } and 12.95 ± 1.43 % at T _{ 1 }, for subacute patients, and 16.06 ± 1.23 % at T _{ 0 } and 13.13 ± 0.97 % at T _{ 1 }, for chronic patients. The E _{ RS } values were comparable to those found with the parameters values chosen showing that the model is robust for variation of the parameters. (PDF 89 kb)
Additional file 3: Figure S3.
Evaluation parameters. The bar plots show average and standard error of the Evaluation parameters for real trajectories (left bars) and the simulated trajectories (right bars) both for T _{ 0 } (dark colors) and T _{ 1 } (light colors). Red and blue colors code subacute and chronic patients. Asterisks (*) indicate significant differences (Wilcoxon signedrank test, p < 0.05) between T _{ 0 } and T _{ 1 } for subacute (red), chronic (blue), and modeled trajectories (grey). (PDF 273 kb)
Additional file 4: Figure S4.
A) Correlation matrix for Modelbased parameters and Evaluation parameters. B) Correlation matrix for Modelbased parameters and clinical scores. (PDF 188 kb)
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Panarese, A., Pirondini, E., Tropea, P. et al. Modelbased variables for the kinematic assessment of upperextremity impairments in poststroke patients. J NeuroEngineering Rehabil 13, 81 (2016). https://doi.org/10.1186/s1298401601879
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DOI: https://doi.org/10.1186/s1298401601879