Dynamic cerebral autoregulation (dCA) is impaired following stroke. However, the relationship between dCA, brain atrophy, and functional outcomes following stroke remains unclear. In this study, we aimed to determine whether impairment of dCA is associated with atrophy in specific regions or globally, thereby affecting daily functions in stroke patients.
We performed a retrospective analysis of 33 subjects with chronic infarctions in the middle cerebral artery territory, and 109 age-matched non-stroke subjects. dCA was assessed via the phase relationship between arterial blood pressure and cerebral blood flow velocity. Brain tissue volumes were quantified from MRI. Functional status was assessed by gait speed, instrumental activities of daily living (IADL), modified Rankin Scale, and NIH Stroke Score.
Compared to the non-stroke group, stroke subjects showed degraded dCA bilaterally, and showed gray matter atrophy in the frontal, parietal and temporal lobes ipsilateral to infarct. In stroke subjects, better dCA was associated with less temporal lobe gray matter atrophy on the infracted side ( = 0.029), faster gait speed ( = 0.018) and lower IADL score (0.002). Our results indicate that better dynamic cerebral perfusion regulation is associated with less atrophy and better long-term functional status in older adults with chronic ischemic infarctions.
Citation: Aoi MC, Hu K, Lo M-T, Selim M, Olufsen MS, Novak V (2012) Impaired Cerebral Autoregulation Is Associated with Brain Atrophy and Worse Functional Status in Chronic Ischemic Stroke. PLoS ONE 7(10): e46794. doi:10.1371/journal.pone.0046794
Editor: Thiruma V. Arumugam, University of Queensland, Australia
Received: March 19, 2012; Accepted: September 7, 2012; Published: October 11, 2012
Copyright: © Aoi et al. This is an open-access article distributed under the terms of the Creative Commons Attribution License, which permits unrestricted use, distribution, and reproduction in any medium, provided the original author and source are credited.
Funding: This study was supported by The National Institutes of Health - National Institute of Neurological Disorders and Stroke (NIH - NINDS) (www.ninds.nih.gov/) (R01-NS045745), The National Institutes of Health - National Institute of Neurological Disorders and Stroke (NIH - NINDS), The National Institutes of Health - National Institute of Neurological Disorders and Stroke - The Small Business Technology Transfer (NIH - NINDS - STTR) (1R41NS053128-01A2), The National Institutes of Health - National Institute of Aging (NIH-NIA) (1R01-AG0287601A2), (1P30AG028717-01A2), American Diabetes Association (1-06-CR-25), and The National Institutes of Health - National Institute of Aging (NIH-NIA) (OAIC1P30AG028717-01A2). MCA and MSO were supported in part by the National Science Foundation/Division of Mathematical Sciences-0616597 and Kirschstein-National Research Service Award 5 T32 AG023480 - 05 grants. MCA also received support from the Center for Quantitative Sciences in Biology at North Carolina State University. KH was supported by The National Institutes of Health - The National Heart, Lung, and Blood Institute (NIH - NHLBI) K99HL102241, NIH-R00HL102241, P30AG028717, and the KL2 Medical Research Investigator Training grant (5 KL2 RR025757-02) of Harvard Catalyst, The Harvard Clinical and Translational Science Center (Award #UL1 RR 025758 and financial contributions from Harvard University and its affiliated academic health care centers). MS receives grant support from the The National Institutes of Health - National Institute of Neurological Disorders and Stroke (NIH/NINDS) (RO1 NS057127). VN and KH were also supported by Grant Number UL1 RR025758-Harvard Clinical and Translational Science Center, from the National Center for Research Resources and a Beth Israel Deaconess Medical Center, Clinical Research Center Grant (MO1-RR01302). MTL was supported by National Science Council (NSC) (Taiwan, ROC) grants 100-2221-E-008-008-MY2 and 100-2911-I-008-001. The funders had no role in study design, data collection and analysis, decision to publish, or preparation of the manuscript.
Competing interests: The authors have declared that no competing interests exist.
Cerebral autoregulation (CA) modulates cerebral blood flow in order to meet regional perfusion demands despite variations in arterial blood pressure (BP) associated with daily activities . Dynamic CA (dCA) refers to the rapid response of cerebral vasculature to transient BP fluctuations. Several mechanisms are involved in dCA, regulating cerebrovascular resistance through dilation and constriction of cortical and pial arterioles . Autoregulation is affected by age-related cerebro-microvascular diseases such as hypertension  and diabetes , and is damaged by ischemic stroke both acutely – and chronically .
Both impaired dCA , , assessed in the acute stroke period, and stroke-associated gray matter (GM) atrophy ,  are associated with deficits in functional outcomes. However, the impact of chronically impaired dCA on brain atrophy, as well as its long-term effects on functional status in patients with ischemic stroke, remain unknown. If post-stroke dCA directly impacts GM atrophy and functional status, then interventions aimed at improving dCA function may provide an additional modality for clinicians to mitigate long-term functional deficits in stroke patients.
Noninvasive assessment of dCA often entails examining the coupling between continuous BP and cerebral blood flow velocity (BFV), measured by transcranial Doppler ultrasound (TCD). However, finding computational methods for the accurate quantification of this relationship is a challenge to reliable dCA assessment. Multimodal pressure-flow (MMPF) analysis , – can better quantify the nonlinear relationship between non-stationary BP and BFV signals than traditional transfer function methods  using spontaneous BP-BFV fluctuations during baseline conditions .
This study applied the MMPF-derived dCA measure to examine the relationship between dCA, regional brain tissue volumes, and functional status in a retrospective analysis of elderly subjects with chronic large vessel infarctions in the middle cerebral artery (MCA) territory, and in age-matched non-stroke subjects. We hypothesize that worse perfusion regulation is associated with enhanced gray matter atrophy in the temporal lobe, and worse long-term functional status in the elderly with chronic ischemic infarctions.
All subjects signed informed consent and the study was approved by the Institutional Review Board at Beth Israel Deaconess Medical Center (BIDMC). Participants were recruited from community advertisement, Beth Israel Deaconess Medical Center, Joslin Diabetes Clinic patient registries and from the Harvard Cooperative Program on Aging research subject registry.
The data for this retrospective analysis of 142 subjects were selected from a database of records prospectively collected at the Syncope and Falls in the Elderly Laboratory and the Magnetic Resonance Imaging Center at BIDMC. The database was composed of records from three completed projects spanning January 2002 to February 2008: Cerebral vasoregulation in the elderly with stroke (March 2003–April 2005); Cerebral vasoregulation in diabetes (January 2002–December 2005); and Cerebral perfusion and cognitive decline in type 2 diabetes (January 2006–December 2008). Grant numbers and awarding institutions are provided in the financial disclosures section. All stroke subjects included in the current project were recruited for the vasoregulation in the elderly study while diabetic non-stroke subjects were from the vasoregulation in diabetes and cognitive decline in diabetes studies. Non-diabetic non-stroke subjects were recruited in all three studies. The subjects were selected for the present cohort, only if they completed both TCD and MRI measurements, and met the inclusion/exclusion criteria detailed below and in , .
Included stroke subjects had large vessel hemispheric MCA infarcts affecting 1/3 of the MCA territory documented by CT or MRI during the acute event, defined according to the Trial of ORG 10172 in Acute Stroke Treatment (TOAST) criteria  after completion of diagnostic work up, i.e., patients with MCA infarcts who had clinical and radiographic (duplex imaging or arteriography) findings of either significant (50%) stenosis or occlusion of an appropriate extracranial (i.e., carotid) or intracranial artery or branch cortical artery due to presumed atherosclerosis. Diagnostic studies excluded potential sources of cardioembolism. Clinical findings included those of cerebral cortical impairment (aphasia, neglect, or restricted motor involvement). A history of intermittent claudication, TIAs in the same vascular territory, a carotid bruit, or diminished pulses was used to support the clinical diagnosis. Infarcts greater than 1.5 cm in diameter on CT or MRI were considered to be of potential large-artery atherosclerotic origin. Subjects were required to be 6 months post-stroke, in a clinically stable condition defined by a neurological exam, NIH Stroke Scale (NIHSS) 5, and able to walk unassisted (modified Rankin Scale (mRS)4) upon admission to the study.
All diabetic subjects were required to be diagnosed with type-II diabetes mellitus (DM) and to have been treated for at least 1 year prior to participation. Non-diabetic controls were age- and sex- matched to diabetic and stroke subjects from their respective studies with no clinical history of stroke and no focal deficits on neurological examination. Non-diabetic participants were required to have normal fasting glucose.
Subjects were excluded if they had intracranial or subarachnoid hemorrhage on MRI or CT or carotid artery stenosis (for control group, over 50% by medical history and MR angiobgraphy and for the stroke group, bilateral stenosis or stenosis contralateral to stroke). Other exclusion criteria included myocardial infarction within 6 months and other clinically important cardiac diseases; arrhythmias; significant nephropathy; kidney or liver transplant; renal or congestive heart failure; type I DM; or neurological or other systemic disorders. Incompatibility with 3 Tesla MRI, including claustrophobia, metal implants, pacemakers, and arterial stents was also an excluding factor.
Collectively, the three studies recruited 358 subjects (157 healthy controls, 115 diabetic controls, 86 stroke). We excluded 145 subjects (71 healthy control, 33 diabetic control, 41 stroke) because they either withdrew consent, they met exclusion criteria (listed above), or they did not get permission from their primary care provider. Of those subjects excluded, 24 subjects (14 healthy controls, 8 diabetic controls, 2 stroke) were excluded due to a poor temporal insonation window. From the remaining 213 subjects, 142 of them (52 healthy control, 57 diabetic control, 33 stroke) had complete TCD and MRI recordings and were used for the final analysis in the present study. Subjects with diabetes, hypertension, or both were included as part of the non-stroke group in order to control for dCA impairment associated with risk factors related to stroke. Demographic information of the selected cohort is listed in Table 1.
The stroke group consisted of 33 subjects that were 6.715.17 (mean SE) years post acute event. The non-stroke group consisted of 109 age- and sex-matched individuals. There were 23 stroke and 36 non-stroke (12 control, 24 diabetic) participants with hypertension defined as receiving treatment for hypertension, or average BP140 or 90 mmHg on 24-hour ambulatory home monitoring. There were 57 non-stroke participants receiving treatment for type 2 diabetes mellitus for 5 years. Antihypertensive medications were tapered and withdrawn for 3 days prior to the study. Glycemic control medications were allowed.
Transcranial Doppler Studies.
Experiments were conducted in the morning after a thirty-minute rest during instrumentation. Baseline recordings of 5–10 minutes were collected during resting conditions when subjects were supine, awake and breathing regularly at their normal respiratory frequency. Vasoreactivity to CO2 (CO2R) was measured using 3 minutes of hyperventilation followed by 3 minutes re-breathing 5% CO2 in an air bag. Vasoreactivity was calculated as the slope of the regression of CO2 on BFV over baseline, hyperventilation, and rebreathing conditions. BFVs in both MCAs were measured from trans-temporal windows using TCD (MultiDop X4; Neuroscan, Sterling, VA). BP was recorded from the finger using the volume-clamp technique with a Finapres device (Finapres, Ohmeda Monitoring Systems, Englewood, CO) and corroborated by sphygmomanometer measurements. BP, BFV, respiration and end-tidal CO2 measurements (Capnomac Ultima, Ohmeda Monitoring Systems, Englewood, CO) were recorded at 500 HZ. Signals were decimated to 50 Hz before analysis.
Brain volumes and magnetic resonance imaging.
The MRI studies were performed on a 3-Tesla GE Signa Vhi or Excite MRI scanner using a quadrature and phase array head coils (GE Medical Systems, Milwaukee, WI). Anatomical 3D magnetization prepared rapid gradient echo (MP-RAGE) images were used to quantify brain volumes with the Statistical Parametric Mapping software (SPM, University College,A London, UK) using spatial normalization and tissue classification. An anatomical template (Laboratory of Neuro Imaging, University of California, Los Angles, USA) was applied to measure GM and white matter (WM) in frontal, temporal, parietal, and occipital lobes. Normalized volumes (regional volume/global intracranial volume, cm3/cm3) of GM, and WM were used for analysis. Vessel diameters were derived from 3D MR angiography (time of flight, TOF) using the Medical Image Processing, Analysis, and Visualization (MIPAV) software from the Biomedical Imaging Research Services Section, NIH, Bethesda, MD, at 3 locations and averaged. Diameters Internal carotid arteries (ICA) and MCAs were computed from a single-slice transverse view with conservatively estimated accuracy (0.4 mm), based on the image resolution.
Functional status was assessed in both stroke and non-stroke groups by gait speed (measured by a 12-minute walking test at preferred walking speed), Instrumental Activities of Daily Living  (IADL) survey, and the Mini Mental State Exam (MMSE). The stroke group was also assessed by NIHSS, and mRS.
The MMPF analysis for this study was performed according to the following four major steps:
- Decomposition of BP and BFV signals into multiple empirical modes.Central to the MMPF method is the Hilbert-Huang transform . This approach decomposes the original signal into empirical modes by a “sifting” algorithm  which adaptively extracts narrow-band, zero mean (but not necessarily stationary) components of the original BP and BFV time series.
- Selection of empirical modes for dominant oscillations in BP at 0.1–0.3 Hz and corresponding oscillations in BFV.In order to determine a meaningful phase relationship between the BP and BFV time series, empirical modes from both series must be selected from within the same frequency band. Previous studies have shown that dCA can be assessed from respiratory-induced pressure-flow variations during spontaneous respiration , , , . Therefore, the modes used for further analysis were selected in order to correspond to the respiratory frequency range of 0.1–0.3 Hz.
- Calculation of instantaneous phases of extracted BP and BFV oscillations.Since each empirical mode has zero mean and is sufficiently narrow-band, the complex part of each mode can be calculated by the Hilbert transform . The instantaneous phase of BP or BFV oscillations is obtained from the inverse tangent transform of the ratio of the real and complex parts of the signal.
- Calculation of the mean BP-BFV phase difference (), as the dCA measure.The arithmetic mean of the difference in the phases of extracted BP and BFV oscillations was calculated and served as the metric by which we assessed dCA. Larger corresponds to better dCA function , , .
For all subjects, MRI and TCD measurements were made on both left and right sides and analyses were conducted by stroke side and non-stroke side. Since non-stroke subjects did not have an affected side, each non-stroke subject was randomly assigned a ÒstrokeÓ side (RND1) and a Ònon-strokeÓ side (RND2). The side assignment was implemented in order to have a left-side-stroke/right-side-stroke probability that approximately matched the distribution of the stroke group. Univariate group differences were determined by one -, or two-tailed t-test, or test where appropriate. Within-group differences between sides in brain volumes, blood flow velocity, the dCA measure (), and ICA and MCA diameters were determined by 1-sided Wilcoxon signed-rank test.
To constrain the number of variables under consideration, regression analyses were limited to those areas directly affected by stroke (i.e. MCA territory on the stroke side/RND1). Linear regression models were tested for the effects of on GM volumes, on functional measures and GM volumes on functional measures. With each model, we examined the primary independent variable (either or GM volume) was examined for a significant effect separately for stroke and non-stroke subjects.
Regression parameters were estimated using the traditional least squares estimator as well as the Theil-Sen robust regression estimator ,  with outlier skipping by the orthogonal projection method (TSOP). This robust regression estimator down-weights response outliers and high leverage points observed in our data .
Robust regression parameter inference, including simultaneous 95% confidence intervals and hypothesis test statistics, was estimated by bootstrapping of observations. For each robust regression, bootstrapping consisted of n = 600 resamples of the stroke group, with replacement, of the multivariate observations. Regression parameter estimates, standard errors, bootstrap confidence intervals, and hypothesis test statistics were calculated using functions written by R.R. Wilcox  in the rallfun.v-14 package (downloaded from www-rcf.usc.edu/rwilcox/ on 6/19/11) for the statistical computing software R . The Theil-Sen estimates were calculated using the tsreg() function embedded within the opreg() function. Bootstrap confidence intervals were calculated using the regci() function. Default settings were used for all functions. Linear models for robust regression controlled for age, mean blood pressure, sex, BMI and infarct volume.
Relationships between GM and IADL and between and IADL were tested by logistic regression. The IADL scores 3, which were present in 7 subjects, were grouped into a single category. Statistical control variables were included based on the presence of significant correlations with brain matter volumes, functional status measurements or . The resulting models were adjusted for age, sex, mean BP, infarct volume, and body mass index (BMI).
For groups of hypothesis tests that included multiple variables (differences between groups and between sides), the threshold of significance was adjusted to maintain a false discovery rate  of 0.05. Statistical inference was computed in JMP (SAS Institute. Cary, NC, USA).
Effects of stroke on functional status, brain volumes, and dCA
Demographic characteristics, mean BP, MCA and ICA diameters on the non-stroke side, mean BFV and CO2 vasoreactivity and laboratory results were similar between the stroke and non-stroke groups (Table 1). Stroke subjects had worse scores on performance and cognitive measures (IADL , MMSE ) and slower gait speed (). In stroke subjects, frontal, temporal and parietal lobe volumes were significantly smaller on the stroke side as compared to the non-stroke side, and to the RND1 and RND2 sides of non-stroke subjects (Table 2). Mean BFV and CO2 vasoreactivity was not significantly different between sides within either group. There were no significant differences in any measures between the RND1 and RND2 sides of non-stroke subjects.
BP-BFV phase shift () was smaller in stroke subjects compared to non-stroke subjects (Table 1, stroke side: ; non-stroke side: ), but was not different between stroke and non-stroke sides. In the non-stroke group, non-diabetic subjects had larger than diabetic subjects (RND1: ; RND2: ), who had similar to stroke subjects. BP-BFV phase shift was not significantly associated with age; mean, systolic, or diastolic BP; hypertension diagnoses or treatment; mean BFV; CO2 vasoreactivity; left/right stroke side; glucose levels; hematocrit; hemoglobin A1C levels; BMI; ICA or MCA diameters; total cholesterol, LDL or triglycerides.
The fraction of subjects with either current or previous smoking history was significantly different for stroke and non stroke groups (Table 1). Neither smoking status nor packs per year (pack years) were significantly correlated () with gait speed, or GM volumes. Therefore, smoking data was not included in further analyses.
Associations between dCA, regional brain volumes, and functional status
Pressure-flow phase shift and brain volume.
Using least squares regression, a larger was associated with larger temporal lobe GM volume in stroke subjects (model fit: adjusted () = 0.73, , effect test: -ratio , ) after controlling for age, sex, mean BP, BMI, and infarct volume, but not in non-stroke subjects (model fit: , , Effect test: -ratio , ). The relationship between and temporal lobe GM, independent of age, sex, mean BP, BMI, and infarct volume is shown in Fig. 1. There were no significant associations between and temporal WM or between and GM or WM volumes in frontal, parietal, or occipital regions.
Residuals of least squares regression on relative temporal lobe gray matter (GM) volume against BP-BFV phase difference (). Regression included age, BMI, mean BP, sex and infarct volume for stroke side of the stroke group plotted against blood pressure-blood flow velocity (BP-BFV) phase difference for stroke (A) and non-stroke (B) sides. Cyan lines indicate least squares regression line for BP-BFV phase difference on temporal GM residuals in stroke subjects, and 95% prediction interval.
In agreement with the least squares estimates, the Theil-Sen estimates showed a significant effect ( = 0.047) of on temporal lobe GM for stroke subjects (Table 4) after controlling for age, sex, mean BP, BMI, and infarct volume, but not for other brain regions.
Pressure-flow phase shift and functional status.
Using the least squares estimator, a larger was associated with faster gait speed for stroke subjects (model fit: , , Effect test: -ratio , ) after controlling for age, sex, mean BP, BMI, and infarct volume, but not for non-stroke subjects (model fit: , , Effect test: -ratio , ). The relationship between and gait speed, independent of age, sex, mean BP, BMI, and infarct volume is shown in Fig. 2A.
A: the residuals from least squares regression of age, BMI, mean BP, sex and infarct volume for stroke side of the stroke group, on gait speed plotted against stroke-side blood pressure-blood flow velocity (BP-BFV) phase difference. Cyan lines indicates least squares regression for BP-BFV phase difference on gait speed residuals in stroke subjects and 95% prediction interval. B: BP-BFV phase difference for stroke and non-stroke subjects as a function of score on the instrumental activities of daily living (IADL) survey. Error bars indicate standard error.
The Theil-Sen estimate for the relationship between and gait speed did not meet the threshold for a significant effect, but was found to be marginally significant ( = 0.097, Table 4) when controlling for age, sex, mean BP, BMI and infarct volume. The -value of the test was considerably reduced ( = 0.067) when infarct volume was not included in the regression.
Ordinal logistic regression showed that a larger was associated with a better daily functionality (i.e., lower IADL) for stroke subjects (Lack of fit: , , Effect likelihood ratio test: , ) (Fig. 2B) after controlling for age, sex, mean BP, BMI and infarct volume but there was no significant association between and IADL in non-stroke subjects (Lack of fit: , , Effect likelihood ratio test: , ). No associations were found between and MMSE, mRS or NIHSS.
Regional brain volumes and functional status.
In contrast with our findings of associations between and temporal GM, and between and functional status in stroke subjects, no significant associations were found between temporal GM and gait speed (model fit: = 0.51, = 0.0004, Effect test: -ratio , ) after controlling for age, sex, mean BP, BMI and infarct volume using the least squares estimator. However, faster gait speed was associated with larger temporal lobe GM volumes if infarct volume was not included in the regression equation for both stroke (model fit: = 0.62, , Effect test: -ratio , ) and non-stroke (model fit: = 0.12, , Effect test: -ratio , ) subjects. This effect was significantly stronger in stroke subjects than for non-stroke subjects (Effect test of interaction: -ratio , ).
Similar to our results with least squares regression, the Theil-Sen estimate for a relationship between gait speed and temporal GM was marginally significant, ( = 0.08) when infarct volume was included, with a smaller -value ( = 0.06) when infarct volume was not included.
IADL was not significantly associated with temporal GM (Lack of fit: , , Effect likelihood ratio test: , ) after controlling for age, sex, mean BP, BMI and infarct volume. However, larger temporal lobe GM on the stroke side was associated with better functionality (i.e. lower IADL) for stroke subjects (Lack of fit: , , Effect likelihood ratio test: , ) but not for non-stroke subjects (Lack of fit: , , Effect likelihood ratio test: , ). Brain volumes were not associated with MMSE or NIHSS.
Regional brain volumes, gait speed, and infarct volume.
In order to examine the confounding effect of infarct volume on linear regressions observed above, linear regressions of infarct volume on gait speed and temporal lobe GM were examined, after correcting for age, sex, mean BP and BMI. Least squares regression showed that larger infarct volumes were associated with significantly slower gait speed (model fit: = 0.505, 0.0004, Effect test: -ratio = −5.31, 0.0001) and smaller temporal GM volumes (model fit: = 0.68, 0.0001, Effect test: -ratio = −7.93, 0.0001). On the other hand, robust regression showed only a modest effect of infarct volume on temporal GM ( = 0.077) and none for gait speed ( = 0.51).
This study examined the relationships among dCA, brain structural volumes, and functional status in subjects with chronic ischemic stroke using a nonlinear dCA assessment computed using the MMPF method. Both traditional least squares regression and robust regression were used to test the hypothesis that better dCA function is associated with less GM atrophy and better functional status. Supporting this hypothesis, smaller was associated with smaller temporal lobe GM, slower gait speeds, and higher IADL (lower function), independent of age, sex, mean BP, and BMI.
Poor clinical outcomes have been shown to be associated with impaired dCA following both brain injury – and acute ischemic stroke , . This study presented evidence indicating that not only is worse functional status post-stroke concomitant with impaired dCA, but the degree of dCA impairment is negatively correlated with functional performance (Fig. 2).
Atrophy of brain tissue continues following the acute stroke period and extends from periinfarct zones to contralateral and remote cortical and subcortical regions that are functionally connected to the infarct site . Supporting this notion are findings of impaired vascular reactivity in regions distant from the infarct site in patients with chronic ischemic infarctions . We also noted a consistent pattern of GM atrophy, independent of the specific infarct location, in the ipsilateral frontal, parietal and temporal lobes extending beyond the affected MCA territory (Table 2).
Both impaired CA  and GM atrophy ,  following stroke have been associated with cognitive impairment. Therefore, chronic impairment of autoregulation may affect perfusion redistribution during daily activities , –, contributing to GM atrophy and influencing long-term recovery after stroke.
In the present study, although all MCA-territory brain regions showed significant atrophy for stroke subjects, the relationships between dCA impairment, GM atrophy, and functional status were most prominent for temporal lobe GM. These relationships were not observed in age-matched, diabetic, or non-diabetic non-stroke subjects, and were independent of BP. However, diabetic subjects also had impaired dCA compared to healthy nonstroke subjects, which suggests that associations between dCA, functional impairment, and temporal lobe GM are stroke-specific and not due to normal aging or stroke-independent dCA impairment.
Temporal lobe structures such as the insular cortex and amygdala are key centers of the autonomic network , playing a role in vascular resistance and sympathetic modulation of dCA . Both autoregulation , – and autonomic regulation ,  are altered following stroke, and sympathetic activity has been shown to affect dCA , although its precise role is contended , . Damage to the insular cortex in particular is associated with autonomic dysfunction , ,  and poor long-term prognosis  in stroke subjects. Medial temporal lobe atrophy is also associated with greater incidence of post-stroke dementia . Thus, temporal lobe atrophy may persistently affect dCA via its influences on autonomic function, in addition to its more direct effects on functional performance. A more detailed analysis of the temporal lobe structures is needed to determine if specific regions of the temporal lobe are responsible for its role in the dCA -temporal GM-functional status relationship found in the current study.
Disrupted autonomic regulation after stroke may also influence the clinical outcomes measured in this study, independent from dCA. Sympathetic reflex activity is attenuated with chronic stroke and this attenuation is correlated with functional motor capacity . Similarly, pathological sympathetic activity has been shown to be associated with poor long-term outcomes in subjects with thromboembolic stroke . The potential role of autonomic function on the dCA - brain atrophy - functional outcomes relationship should be directly examined in stroke subjects. In this regard, future studies should consider BP-BFV coupling over frequency bands more directly associated with autonomic activity .
We hypothesize that treatments aimed at the improvement of dCA may play a role in optimizing the functional performance and quality of life in elderly people with chronic ischemic stroke. Therefore, the dCA status and the potential effects of treatments (such as antihypertensive medications , ) on dCA function and functional outcomes should be considered in the overall treatment strategy for patients with chronic stroke. For example, angiotensin receptor blockers (ARB's) have been shown to prevent vascular dementia in elderly subjects  and brain atrophy in hypertensive subjects , and they are significantly more effective at preventing stroke in hypertensive patients than other blood-pressure-lowering medications . They have not been shown to lower risk of recurrent stroke, however, . Since some component of the neuroprotective effects of ARBs may be independent of their BP-lowering effects , , the neuroprotective effects of ARBs may be acting through their ability to improve autoregulatory function. Therefore if, as the present study suggests, there is a connection between dCA, brain atrophy and functional status following stroke, treatment with ARBs may be an effective strategy for stroke patients to preserve functional status, even in the absence of hypertension. While ARB's have been shown to improve static cerebral autoregulation in hypertensive rats , investigations of the effects of ARBs on dCA are needed.
The results of least squares regression were in agreement with robust regression estimates for the relationship between and temporal lobe GM. However, in part due to the presence of outliers, the associations between and gait speed were more tenuous, and the correlation between temporal lobe GM and gait speed was only marginally significant based on robust regression. The latter results are surprising, as degree of GM atrophy is known to coincide with degree of functional impairment. For instance, Lee  demonstrated that brain atrophy negatively impacts functional recovery, as measured by mRS, where “acceptable” outcomes were operationalized as mRS 4. In the current study, mRS 4 was a necessary condition of inclusion. The Lee sample also included individuals with more severe strokes than in the current study, as measured by NIHSS. Furthermore, the number of participants with IADL scores larger than 2 was limited in our study. Therefore, a larger prospective study that draws upon subjects from a population-based sample of people with various types of strokes may be beneficial to verifying the findings of this study.
Including infarct volume in the linear models had a considerable effect on robust regression results. When including infarct volume, the regressions of on gait speed and temporal lobe GM on gait speed were marginally significant (0.050.1) These associations were somewhat stronger when infarct volume was excluded from the models (0.07 for both). Robust regression estimators tend to have poor asymptotic efficiency . Consequently, the small sample size of this study makes our results susceptible to type II error, particularly with a larger number of covariates. Thus, the efficiency of the estimator may help explain the impact of infarct volume on the models in spite of the lack of a robust association between gait speed and infarct volume ( = 0.51). Therefore, we view our results with both the least squares and robust regression estimators to be in support of our hypothesis that there is an interaction between dCA, brain atrophy, and functional status following stroke, although we concede that studies with larger and more diverse samples of stroke subjects are necessary in order to verify our results.
The size and variability of the sample may also explain why no significant differences in CO2 reactivity between groups were detected (Table 1). In agreement with previous findings of depressed CO2 reactivity for stroke subjects , the group mean of CO2 reactivity was lower in stroke subjects than in non-stroke subjects. However, the between-group difference was not significant due to the large standard errors within both groups.
Due to the retrospective nature of the present study, the sample selected for analysis was not population-based. Specifically, our non-stroke group included individuals with diabetes, hypertension, or both while all stroke subjects were non-diabetic. However, diabetes is a major risk factor for stroke and hypertension , . Cardiovascular risk factors, such as hypertension and diabetes are known to alter endothelial function and have adverse effects on cerebral vasoreactivity. Both diabetes and hypertension are shown to degrade dCA , , and dCA was impaired in diabetic subjects in the present study. Importantly, recent work has suggested that impairment of CA precedes stroke , . Inclusion of individuals with risk factors for stroke (e.g., DM and hypertension) within the control group, but not in the stroke group, allowed us to determine the extent to which our results were a reflection of the interactions between dCA impairment and effects due to stroke versus the interactions between dCA impairment, stroke and effects due to cardiovascular risk factors that are predictive of stroke. Thus, it is conceivable that preexisting impairment of CA may influence GM atrophy and functional recovery following stroke. Leveraging the notion that dCA impairment precedes stroke, we may posit that impairment of dCA may alter neurovascular coupling in GM, thus making the stroke-affected regions vulnerable to transient cerebral blood flow fluctuations, and altering processes governing connectivity for neuroregeneration and functional recovery. Future work should include the analysis of a population-based sample of larger size.
The study design has also limited the elucidation of causality between impaired cerebral autoregulation, brain tissue loss and poor functional outcomes in stroke patients. Since stroke itself can cause impairment of dCA, brain tissue loss and worse functional outcomes, the cross-sectional study design cannot demonstrate a causal link between dCA, tissue loss and functional outcome. Therefore, future work should include a longitudinal study that would evaluate the time course and relationship between cerebral autoregulation and functional outcomes.
There are likely associations between dCA, temporal lobe GM, gait speed, and IADL, indicating that dCA may impact GM atrophy and functional recovery following stroke. The relationships between dCA, temporal lobe GM and functional status were independent of age, sex, BMI, mean BP and mean BFV, but it is unclear how infarct volume is associated with these parameters. Therefore, dCA impairment may be an important factor underlying perfusion adaptation to daily activities and progression of regional atrophy and functional recovery in patients with stroke.
The authors would like to thank the reviewers for their helpful comments on the improvement of this manuscript. We would also like to thank Sara Monti for help with the preparation of this manuscript.
Conceived and designed the experiments: VN KH. Performed the experiments: VN. Analyzed the data: MCA KH VN. Contributed reagents/materials/analysis tools: KH MTL. Wrote the paper: MCA KH VN. Provided expert interpretation of data analysis and edited the manuscript: MS MSO.
- 1. Lassen N (1959) Cerebral blood ow and oxygen consumption in man. Physiol Rev 39: 183–238.
- 2. Paulson O, Strandgaard S, Edvinsson L (1990) Cerebral autoregulation. Cerebrovasc Brain Metab Rev 2: 161–192.
- 3. Novak V, Yang A, Lepicovsky L, Goldberger A, Lipsitz L, et al. (2004) Multi-modal pressure-ow method to assess dynamics of cerebral autoregulation in stroke and hypertension. Biomedical Engineering Online 3: 39.
- 4. Last D, Alsop D, Abduljalil A, Marquis RP, de Bazelaire , et al. (2007) Global and regional effects of type 2 diabetes on brain tissue volumes and cerebral vasoreactivity. Diabetes Care 30: 1193–1199.
- 5. Reinhard M, Wihler C, Roth M, Harloff A, Niesen W, et al. (2008) Cerebral autoregulation dynamics in acute ischemic stroke after rtPA thrombolysis. Cerebrovasc Dis 26: 147–155.
- 6. Dawson S, Blake M, Panerai R, Potter J (2000) Dynamic but not static cerebral autoregulation is impaired in acute ischaemic stroke. Cerebrovasc Dis 10: 126–132.
- 7. Dawson S, Panerai R, Potter J (2003) Serial changes in static and dynamic autoregulation after acute ischaemic stroke. Cerebrovac Dis 16: 69–75.
- 8. Eames P, Blake M, Dawson S, Panerai R, Pottter J (2002) Dynamic cerebral autoregulation and beat-to-beat blood pressure control are impaired in acute ischaemic stroke. J Neurol Neurosurg Psychiatry 72: 467–472.
- 9. Alvarez F, Segura T, Castellanos M, Leira R, Blanco M, et al. (2004) Cerebral hemodynamic reserve and early neurologic deterioration in acute ischemic stroke. J Cereb Blood Flow Metab 24: 1267–1271.
- 10. Stebbins G, Nyenhuis D, Wang C, Cox JL, Freels S, et al. (2008) Grey matter atrophy in patients with ischemic stroke with cognative impairment. Stroke 39: 785–793.
- 11. Pohjasvaara T, Mäntylä R, Slaonen O, Aronen H, Ylikoski R, et al. (2000) The effect of brain atrophy on outcome after a large cerebral infarction. Arch Neurol 57: 1295–1300.
- 12. Hu K, Peng C, Czosnyka M, Zhao P, Novak V (2008) Nonlinear assessment of cerebral autoregulation from spontaneous blood pressure and cerebral blood ow uctuations. Cardiovascular Engineering 8: 60–71.
- 13. Lo MT, Hu K, Liu Y, Peng C, Novak V (2008) Multimodal Pressure Flow Analysis: Application of Hilbert Huang Transform in Cerebral Blood Flow Regulation. EURASIP J Appl Signal Processing 2008: 785243.
- 14. Lo MT, Novak V, Peng CK, Liu Y, Hu K (2009) Nonlinear phase interaction between nonstationary signals: A comparison study of methods based on Hilbert-Huang and Fourier transforms. Physical Review E 79: 061924.
- 15. Hu K, Lo MT, Peng C, Liu Y, Novak V (2012) A nonlinear dynamic approach reveals a long-term stroke effect on cerebral blood ow regulation at multiple time scales. PLoS Computation Biology In press.
- 16. Zhao P, Alsop D, AbdulJalil A, Selim M, Lipsitz L, et al. (2009) Vasoreactivity and peri-infarct hyperintensities in stroke. Neurology 72: 643–649.
- 17. Adams HJ, Bendixen B, Kappelle L, Biller J, Love B, et al. (1993) Classification of subtype of acute ischemic stroke: de_nitions for use in a multicenter clinical trial. Stroke 24: 35–41.
- 18. Lawton M, Brody E (1969) Assessment of older people: Self-maintaining and instrumental activities of daily living. Gerontologist 13: 179–186.
- 19. Huang N, Shen Z, Long S, Wu M, Shih H, et al. (1998) The empirical mode decomposition and the Hilbert spectrum for nonlinear and non-stationary time series analysis. Proceedings: Mathematical, Physical and Engineering Sciences 454: 903–995.
- 20. Wu Z, Huang N (2009) Ensemble empirical mode decomposition: A noise assisted data analysis method. Advances in Adaptive Data Analysis 1: 1–41.
- 21. Hu K, Lo MT, Peng C, Novak V, Schmidt E, et al. (2009) Nonlinear pressure-ow relationship is able to detect asymmetry of brain blood circulation associated with midline shift. Journal of Neurotrauma 26: 227–233.
- 22. Hu K, Peng C, Huang N, Wu Z, Lipsitz L, et al. (2008) Altered phase interactions between spontaneous blood pressure and ow uctuations in type 2 diabetes mellitus: Nonlinear assessment of cerebral autoregulation. Physica A 387: 2279–2292.
- 23. Theil H (1950) A rank-invariant method of linear and polynomial regression analysis. Indagationes Mathematicae 12: 85–91.
- 24. Sen P (1968) Estimate of the regression coefficient based on Kendall's tau. Journal of the American Statistical Association 63: 1379–1389.
- 25. Wilcox R (2005) Introduction to Robust Estimation and Hypothesis Testing. Burlington, MA: Elsevier Academic Press, 2nd edition.
- 26. R Development Core Team (2011) R: A Language and Environment for Statistical Computing. R Foundation for Statistical Computing, Vienna, Austria. Available: http://www.R-project.org. ISBN 3-900051-07-0.
- 27. Benjimini Y, Yekutieli D (2001) The control of the false discovery rate in multiple testing under dependency. Ann Stat 29: 1165–1188.
- 28. Schmidt E, Czosnyka M, Steiner L, Balestreri M, Smielewski P, et al. (2003) Asymmetry of pressure autoregulation after traumatic brain injury. J Neurosurgery 99: 991–998.
- 29. Czosnyka M, Smielewski P, Kirkpatrick P, Laing R, Menon D, et al. (1997) Continuous assessment of the cerebral vasomotor reactivity in head injury. Neurosurgery 41: 11–19.
- 30. Czosnyka M, Smielewski P, Kirkpatrick P, Menon D, Pickard J (1996) Monitoring of cerebral autoregulation in head-injured patients. Stroke 27: 1829–1834.
- 31. Kreamer M, Schormann T, Hagemann G, Qi B, Witte O, et al. (2004) Delayed shrinkage of the brain after ischemic stroke: preliminary observations with voxel- guided morphometry. J Neuroimaging 14: 265–272.
- 32. Novak V, Hu K, Desrochers L, Novak P, Caplan L, et al. (2010) Cerebral ow velocities during daily activities depend on blood pressure in patients with chronic ischemic infarctions. Stroke 41: 61–66.
- 33. Novak V, Last D, Alsop D, Abduljalil AM, Hu K, et al. (2006) Cerebral blood ow velocity and periventricular white matter hyperintensities in type 2 diabetes. Diabetes Care 29: 1529–1534.
- 34. Hajjar I, Zhao P, Alsop D, Abduljalil A, Selim M, et al. (2010) Association of blood pressure elevation and nocturnal dipping with brain atrophy, perfusion and functional measures in stroke and nonstroke individuals. Am J Hypertens 23: 17–23.
- 35. Benarroch E (1997) Central Autonomic Network: Functional Organization and Clinical Correlations. Armonk, NY: Futura Publishing.
- 36. Ogoh S, Brothers M, Eubank W, Raven P (2008) Autonomic neural control of the cerebral vasculature: Acute hypotension. Stroke 39: 1979–1987.
- 37. Sander D, Klingelhöfer J (1995) Stroke-associated pathological sympathetic activation related to size of infarction and extent of insular damage. Cardiovasc Dis 5: 381–385.
- 38. Tokgözoglu S, Batur M, Topçuoglu M, Saribas O, Kes S, et al. (1999) Effects of stroke localization on cardiac autonomic balance and sudden death. Stroke 30: 1307–1311.
- 39. Zhang R, Zuckerman J, Iwasaki K, Wilson T, Crandall C, et al. (2002) Autonomic neural control of dynamic cerebral autoregulation in humans. Circulation 106: 1814–1820.
- 40. van Lieshout J, Secher N (2008) Point:Counterpoint: Sympathetic activity does/does not inuence cerebral blood ow. J Appl Physiol 105: 1364–1366.
- 41. Strandgaard S, Sigurdsson S (2008) Point:Counterpoint: Sympathetic activity does/does not in-uence cerebral blood ow. J Appl Physiol 105: 1366–1368.
- 42. Sander D, Winbeck K, Klingelhöfer J, Etgen T, Conrad B (2001) Prognostic releveance of pathological sympathetic activation after thromboembolic stroke. Neurology 57: 833–838.
- 43. Muslumanoglu L, Aki S, Turkdogan D, Us O, Akyuz G (2004) Involvement of sympathetic reex activity in patients with acute and chronic stroke: A comparison with functional motor capacity. Arch Phys Med Rehabi 85: 470–473.
- 44. Omboni S, Parati G, Di Rienzo M, Wieling W, Mancia G (1996) Blood pressure and heart rate variability in autonomic disorders: a critical review. Clinical Autonomic Research 6: 171–182.
- 45. Sare G, Gray L, Bath P (2008) Effect of antihypertensive agents on cerebral blood ow and ow velocity in acute ischaemic stroke: systemic review of controlled studies. J Hypertens 26: 1058–1064.
- 46. Novak N, Hajjar I (2010) The relationship between blood pressure and cognitive function. Nature Reviews: Cardiology 77: 686–698.
- 47. Hanes D, Weir M (2007) Usefulness of ARBs and ACE inhibitors in the prevention of vascular dementia in the elderly. The American Journal of Geriatric Cardiology 16: 175–182.
- 48. Muller M, van der Graaf Y, Visseren F, Mali W, Geerlings M, et al. (2012) Hypertension and longitudinal changes in cerebral blood ow: The SMART-MR study. Annals of Neurology In press.
- 49. Paapademetriou V, Farsang C, Elmfeldt D, Hofman A, Lithell H, et al. (2004) Stroke prevention with the angiotensin II type 1-receptor blocker candesartan in elderly patients with isolated systolic hypertension: The study on cognition and prognosis in the elderly (SCOPE). Journal of the American College of Cardiology 44: 1175–1180.
- 50. Yusuf S, Diener H, Sacco R, Cotton D, Ounpuu S, et al. (2008) Telmisartan to prevent recurrent stroke and cardiovascular events. New England Journal of Medicine 359: 1225–1237.
- 51. Kumai Y, Ooboshi H, Ago T, Ishikawa E, Takada J, et al. (2008) Protective e_ects of angiotensin II Type 1 receptor blocker on cerebral circulation independent of blood pressure. Experimental Neurology 210: 441–448.
- 52. Ito T, Yamakawa H, Bregonzio C, Torrón J, Falcón-Neri A, et al. (2002) Protection against ischemia and improvement of cerebral blood ow in genetically hypertensive rats by chronic pre-treatment with an angiotensin II AT1 antagonist. Stroke 33: 2297–2303.
- 53. Takada J, Ibayashi S, Ooboshi H, Ago T, Ishikawa E, et al. (2006) Valsartan improves the lower limit of cerebal auto regulation in rats. Hypertension Research 29: 621–626.
- 54. Lee S, Oh C, Han J, Kim CY, Kwon OK, et al. (2010) The effect of brain atrophy on outcome after a large cerebral infarction. Journal of Neurology, Neurosurgery and Psychiatry 81: 1316–1321.
- 55. Maeda H, Matsumoto M, Handa N, Hougaku H, Ogawa S, et al. (1993) Reactivity of cerebral blood ow to carbon dioxide in various types of ischemic cerebrovascular disease: Evaluation by the transcranial Doppler method. Stroke 24: 670–675.
- 56. Simonson D (1988) Etiology and prevalence of hypertension in diabetic patients. Diabetes Care 11: 821–827.
- 57. Hypertension in Diabetes Study (HDS): I. Prevalence of hypertension in newly presenting type 2 diabetic patients and the association with risk factors for cardiovascular and diabetic complications: The Hypertension in Diabetes Study Group. Journal of Hypertension 11: 309–317.
- 58. Klein R, Klein B, Lee K, Cruickshanks K, Moss S (1996) The incidence of hypertension in insulindependent diabetes. Arch Intern Med 156: 622–627.
- 59. New D, Chesser A, Thuraisingham R, Yaqoob M (2002) Cereral artery responses to pressure and ow in uremic hypertensive and spontaneously hypertensive rats. American Journal of Physiology: Heart and Circulatory Physiology 284: H1212–H1216.